Health care provision is increasingly focused on the prediction of patients’ individual risk for developing a particular health outcome in planning further tests and treatments. There has been a steady increase in the development and publication of prognostic models for various maternal and fetal outcomes in obstetrics. We undertook a systematic review to give an overview of the current status of available prognostic models in obstetrics in the context of their potential advantages and the process of developing and validating models. Important aspects to consider when assessing a prognostic model are discussed and recommendations on how to proceed on this within the obstetric domain are given. We searched MEDLINE (up to July 2012) for articles developing prognostic models in obstetrics. We identified 177 papers that reported the development of 263 prognostic models for 40 different outcomes. The most frequently predicted outcomes were preeclampsia (n = 69), preterm delivery (n = 63), mode of delivery (n = 22), gestational hypertension (n = 11), and small-for-gestational-age infants (n = 10). The performance of newer models was generally not better than that of older models predicting the same outcome. The most important measures of predictive accuracy (ie, a model’s discrimination and calibration) were often (82.9%, 218/263) not both assessed. Very few developed models were validated in data other than the development data (8.7%, 23/263). Only two-thirds of the papers (62.4%, 164/263) presented the model such that validation in other populations was possible, and the clinical applicability was discussed in only 11.0% (29/263). The impact of developed models on clinical practice was unknown. We identified a large number of prognostic models in obstetrics, but there is relatively little evidence about their performance, impact, and usefulness in clinical practice so that at this point, clinical implementation cannot be recommended. New efforts should be directed toward evaluating the performance and impact of the existing models.
Click Supplemental Materials under article title in Contents at ajog.org
Medicine, including obstetrics, is increasingly focused on risk-based or personalized medicine: treatment or preventive interventions as well as elaborate or burdening prognostic tests are administered based on a patients’ risk for developing a certain health outcome (prognosis). Identification of patients at high risk can be based on a single risk factor, risk indicator, or predictor (eg, a particular patient characteristic, biomarker, or test result) or on a combination of multiple predictors. The prevailing thought is that combining predictors into a so-called risk prognostic or decision model allows for better risk assessment and patient selection than single predictors, tests, or markers.
Two historical examples of prognostic models in obstetrics are the Apgar score to assess the condition of a newborn baby immediately after birth, and the Bishop score to assess cervical ripeness before and during induction of labor. Both models were developed in the 1950s through 1960s, before the introduction of methodological aspects, now considered important to follow in prognostic research, but are still widely used in clinical practice, presumably because of their relevance and ease of use. Over the years, many prognostic models have been developed and published. The authors of this opinion paper have signaled a rise in the number of prognostic models being published, including for obstetric outcomes, without the corresponding increase in the number of models being applied in practice. The aim of this paper is to give a comprehensive overview of the current status of available prognostic models in obstetrics in the context of the potential advantages of prognostic models, the advocated process of developing and validating models, important aspects to consider when assessing a prognostic model, and how we should proceed on this within the obstetric domain.
Why use prognostic models?
The ultimate goal of risk-based management is to allow for timely diagnosis and prognosis and consequently more effective management. Based on patients’ risks, interventions can be applied to those that potentially benefit most, thereby improving patient outcomes while saving costs and avoiding unnecessary burden by refraining from treatment for individuals unlikely to benefit from a certain intervention. Here, prognostic models can aid in several ways. They may serve as an alert (eg, when a woman or newborn needs immediate medical care), be used for individual decision making (eg, to choose an alternative treatment or refrain from treatment when the chances of success or improvement are low), aid in organizational planning (eg, availability of staff and the operating theater when the risk of an operative delivery is high), or allow for individualized counseling of patients (eg, in the decision of a pregnant woman to opt for external cephalic version). We will first describe the currently available models in obstetrics for potential use.
Available prognostic models in obstetrics
As there was no overview of prognostic models available for potential use, we undertook a systematic review of the literature on this topic adhering to the principles in the PRISMA statement.
We searched MEDLINE through PubMed on July 1, 2012, without language or publication date restrictions to identify papers reporting on the development of a prognostic model in obstetrics. The search strategy was based on terms related to women, pregnancy, and obstetrical topics combined with sensitive and specific methodological filters, allowing efficient identification of publications on prognostic models ( Appendix ; Supplementary Tables 1 and 2 ). We defined a prognostic model as a model that could be used to estimate risks for individual patients, or to distinguish groups of patients at different risks, based on ≥3 predictor variables. Papers were excluded if the described model was to be used for diagnosis of a current condition rather than for predicting a future outcome, or the predicted outcome was outside the field of obstetrics, defined as an outcome concerning the pregnant, laboring, or postpartum woman immediately after delivery, or the fetus (eg, fetal growth restriction), or the neonate immediately after birth (eg, birthweight). Eligible papers were selected by 2 reviewers (C.E.K. and E.S.). Titles and abstracts of all papers identified by the search were scrutinized for eligibility. After 300 abstracts were screened in duplicate, which showed good agreement between both reviewers (kappa statistic = 0.71, indicating that 98.7% of papers were scored the same by both reviewers), the remaining were assessed by 1 reviewer. In case of doubt about eligibility, the paper was discussed with the other reviewer to accomplish a joint decision. Once selected, both reviewers examined the full text papers to see whether they met the inclusion criteria. Disagreements about inclusion at any stage of the selection process were resolved by consensus.
From 10,152 citations, a total of 177 papers met inclusion criteria and described the development of ≥1 obstetric prognostic model ( Figure 1 ). Overall, we identified 263 models for 40 different outcomes. The oldest paper identified was published in 1976. Since then, the number of available papers and prognostic models increased markedly ( Figure 2 ). These findings are consistent with those reported elsewhere for other clinical areas. The marked increase in the number of available obstetrical prognostic models indicates that clinicians and researchers are increasingly interested in risk-based medicine or personalized medicine.
Of the 40 different outcomes that were predicted, there were 15 outcomes for which only 1 model was developed, 14 outcomes for which 2 or 3 models were identified, 6 outcomes for which between 4-10 models were available, and 5 outcomes with ≥10 published models. The 5 most frequently predicted outcomes were preeclampsia (n = 69), preterm delivery (n = 63), mode of delivery (n = 22), gestational hypertension (n = 11), and small-for-gestational-age neonates (n = 10). Among these 5 outcomes, many more models were developed for predicting preeclampsia and preterm delivery than for any other outcome. Both preeclampsia and preterm delivery are highly prevalent conditions in obstetrics (up to, and just over, an incidence of 10%, respectively) and are major causes of adverse outcomes. The prevalence and clinical importance of these conditions and the potential benefits of early (preventive) treatment (aspirin for prevention of preeclampsia and progestagens, pessary or cerclage for prevention of preterm delivery) and organization of care (antenatal corticosteroids, intrauterine transfer to centers with neonatal intensive care facilities) may explain the large number of models developed for these outcomes.
Available prognostic models in obstetrics
As there was no overview of prognostic models available for potential use, we undertook a systematic review of the literature on this topic adhering to the principles in the PRISMA statement.
We searched MEDLINE through PubMed on July 1, 2012, without language or publication date restrictions to identify papers reporting on the development of a prognostic model in obstetrics. The search strategy was based on terms related to women, pregnancy, and obstetrical topics combined with sensitive and specific methodological filters, allowing efficient identification of publications on prognostic models ( Appendix ; Supplementary Tables 1 and 2 ). We defined a prognostic model as a model that could be used to estimate risks for individual patients, or to distinguish groups of patients at different risks, based on ≥3 predictor variables. Papers were excluded if the described model was to be used for diagnosis of a current condition rather than for predicting a future outcome, or the predicted outcome was outside the field of obstetrics, defined as an outcome concerning the pregnant, laboring, or postpartum woman immediately after delivery, or the fetus (eg, fetal growth restriction), or the neonate immediately after birth (eg, birthweight). Eligible papers were selected by 2 reviewers (C.E.K. and E.S.). Titles and abstracts of all papers identified by the search were scrutinized for eligibility. After 300 abstracts were screened in duplicate, which showed good agreement between both reviewers (kappa statistic = 0.71, indicating that 98.7% of papers were scored the same by both reviewers), the remaining were assessed by 1 reviewer. In case of doubt about eligibility, the paper was discussed with the other reviewer to accomplish a joint decision. Once selected, both reviewers examined the full text papers to see whether they met the inclusion criteria. Disagreements about inclusion at any stage of the selection process were resolved by consensus.
From 10,152 citations, a total of 177 papers met inclusion criteria and described the development of ≥1 obstetric prognostic model ( Figure 1 ). Overall, we identified 263 models for 40 different outcomes. The oldest paper identified was published in 1976. Since then, the number of available papers and prognostic models increased markedly ( Figure 2 ). These findings are consistent with those reported elsewhere for other clinical areas. The marked increase in the number of available obstetrical prognostic models indicates that clinicians and researchers are increasingly interested in risk-based medicine or personalized medicine.
Of the 40 different outcomes that were predicted, there were 15 outcomes for which only 1 model was developed, 14 outcomes for which 2 or 3 models were identified, 6 outcomes for which between 4-10 models were available, and 5 outcomes with ≥10 published models. The 5 most frequently predicted outcomes were preeclampsia (n = 69), preterm delivery (n = 63), mode of delivery (n = 22), gestational hypertension (n = 11), and small-for-gestational-age neonates (n = 10). Among these 5 outcomes, many more models were developed for predicting preeclampsia and preterm delivery than for any other outcome. Both preeclampsia and preterm delivery are highly prevalent conditions in obstetrics (up to, and just over, an incidence of 10%, respectively) and are major causes of adverse outcomes. The prevalence and clinical importance of these conditions and the potential benefits of early (preventive) treatment (aspirin for prevention of preeclampsia and progestagens, pessary or cerclage for prevention of preterm delivery) and organization of care (antenatal corticosteroids, intrauterine transfer to centers with neonatal intensive care facilities) may explain the large number of models developed for these outcomes.
Important aspects to consider when appraising models
Table 1 describes some of the important concepts in prognostic model studies. Papers describing a prognostic model should report these items that allow for assessment of model performance and applicability, as well as describe a clear definition of the predictors and outcome, details of the population studied, study design (eg, cohort or case control), sample size, and statistical methods including selection of predictors and handling of missing data. Each model included in the systematic review was thoroughly assessed for methodological development and validation as well as reporting, with the use of a checklist based on the CHARMS checklist and a previously conducted systematic review. Supplementary Table 2 gives an overview of all included models and details of their performance, validity, and applicability.
Concept | Description |
---|---|
Discrimination | How well model discriminates between patients with and without outcome, commonly presented as AUC or concordance index. Both AUC and concordance index provide probability that model will give higher probability of outcome to patients with outcome than patients without outcome, or that patients with higher probability will have outcome sooner. |
Calibration | Agreement between observed outcomes and predictions. For example, in group of patients all with predicted probability of outcome of 20%, incidence of outcome should be 20%. When calibration of model is assessed in different population (see “External validity”), often predicted probabilities are too extreme (usually too high). This can be corrected by shrinkage of model coefficients with shrinkage factor that results in better overall predictions and calibration. |
Internal validity | Process of determining internal validity or reproducibility of prognostic model for underlying population, setting from where development data originated. Techniques include apparent validation (model performance is directly assessed in development data), split-sample validation or cross-validation (sample is [randomly] divided, part of data are used to develop model and part that was not used for development is used to evaluate performance), and bootstrapping (bootstrap samples are drawn with replacement from original study sample, reflecting drawing of study samples from underlying population–each sample is used to develop and evaluate model; difference in performance of model between bootstrap sample and original sample indicates optimism of model that arises since model parameters are optimized for sample). |
External validity | Process of determining external validity or generalizability of prognostic model for populations that are similar to, or related to, development sample population. External validation can be performed by same investigators who developed model, for example in patients more recently attending for care (temporal) or in another hospital or center (geographical) but is preferably done by other, fully independent investigators. |
Presentation of prognostic model | Format in which prognostic model is presented so that it can be used to calculate risks for individual patients or groups of patients. For logistic regression model intercept and regression coefficients should be reported, and for Cox model baseline survival and regression coefficients. In addition to presenting full regression formula, other supplementary formats include nomogram (a graphical presentation of model with lines for scoring points for each predictor and line to obtain risk from sum of points), score chart, and table with predictions for certain groups based on combinations of predictor variables. |
Whether the identified models in obstetrics reported model performance (calibration and discrimination), presented the model such that it could be used by others, gave guidance for clinical use, and were internally or externally validated (or both) is also shown in Table 2 . Of the 263 identified models, 57 (21.7%) were internally validated and only 23 (8.7%) were externally validated ( Figure 2 ). Details of model performance, either apparent or at internal or external validation, included calibration of only 46 models (17.5%), details of discrimination for 165 models (62.7%), and both calibration and discrimination were presented for 45 models (17.1%). A prognostic formula, rule or score that could be used by others was reported for 164 models (62.4%) and guidance for clinical use was discussed for 29 (11.0%).
Outcome | No. of models | Internal validation | External validation | Calibration | Discrimination | Presentation prediction model | Decision recommended |
---|---|---|---|---|---|---|---|
Total | 263 | 57 (21.7%) | 23 (8.7%) | 46 (17.5%) | 165 (62.7%) | 164 (62.4%) | 29 (11.0%) |
Preeclampsia | 69 | 14 (20.3%) | 5 (7.2%) | 8 (11.6%) | 60 (87.0%) | 45 (65.2%) | 9 (13.0%) |
Eclampsia | 1 | 1 (100%) | 0 | 0 | 1 (100%) | 0 | 0 |
Gestational hypertension | 11 | 0 | 0 | 0 | 7 (63.6%) | 9 (81.8%) | 0 |
Preterm delivery | 63 | 15 (23.8%) | 4 (6.3%) | 7 (11.1%) | 34 (54.0%) | 33 (52.4%) | 7 (11.1%) |
Gestational diabetes | 9 | 2 (22.2%) | 1 (11.1%) | 1 (11.1%) | 8 (88.9%) | 3 (33.3%) | 2 (22.2%) |
Insulin treatment for gestational diabetes | 1 | 0 | 0 | 1 (100%) | 0 | 0 | 0 |
Abnormal glucose challenge test | 1 | 0 | 1 (100%) | 0 | 1 (100%) | 1 (100%) | 0 |
Congenital malformations | 3 | 0 | 0 | 0 | 3 (100%) | 0 | 0 |
Small-for-gestational-age neonate | 10 | 3 (30.0%) | 0 | 2 (20.0%) | 6 (60.0%) | 5 (50.0%) | 0 |
Intrauterine growth restriction | 4 | 2 (50.0%) | 0 | 1 (25.0%) | 1 (25.0%) | 4 (100%) | 1 (25.0%) |
Birthweight | 3 | 1 (33.3%) | 2 (66.7%) | 0 | 1 (33.3%) | 3 (100%) | 1 (33.3%) |
Low birthweight | 1 | 1 (100%) | 0 | 1 (100%) | 0 | 1 (100%) | 0 |
Vaginal birth after cesarean | 9 | 4 (44.4%) | 2 (22.2%) | 3 (33.3%) | 4 (44.4%) | 6 (66.7%) | 0 |
Induction of labor | 1 | 0 | 0 | 0 | 1 (100%) | 1 (100%) | 0 |
Successful induction of labor | 8 | 0 | 0 | 0 | 2 (25.0%) | 4 (50.0%) | 0 |
Mode of delivery | 22 | 3 (13.6%) | 5 (22.7%) | 10 (45.5%) | 14 (63.6%) | 18 (81.8%) | 4 (18.2%) |
Time to delivery | 1 | 0 | 0 | 0 | 0 | 0 | 0 |
Successful external cephalic version | 4 | 3 (75.0%) | 3 (75.0%) | 3 (75.0%) | 1 (25.0%) | 4 (100%) | 3 (75.0%) |
Vaginal delivery after external cephalic version | 1 | 1 (100%) | 0 | 0 | 1 (100%) | 1 (100%) | 0 |
Mode of delivery in breech presentation | 1 | 0 | 0 | 0 | 0 | 0 | 0 |
Intraamniotic infection and/or inflammation | 2 | 0 | 0 | 2 (100%) | 2 (100%) | 2 (100%) | 0 |
Clinical infection | 1 | 1 (100%) | 0 | 0 | 1 (100%) | 1 (100%) | 0 |
Histologic signs of infection | 1 | 0 | 0 | 0 | 1 (100%) | 0 | 0 |
Miscarriage or early fetal loss | 2 | 0 | 0 | 0 | 1 (50.0%) | 1 (50.0%) | 0 |
Stillbirth | 3 | 0 | 0 | 0 | 2 (66.7%) | 2 (66.7%) | 0 |
Perinatal mortality or survival | 2 | 1 (50.0%) | 0 | 1 (50.0%) | 0 | 2 (100%) | 0 |
Poor perinatal outcome | 2 | 0 | 0 | 0 | 0 | 1 (50.0%) | 0 |
Hypertensive disorders (combined) or placenta-related complications | 3 | 1 (33.3%) | 0 | 0 | 3 (100%) | 1 (33.3%) | 0 |
Placenta previa | 1 | 0 | 0 | 0 | 1 (100%) | 0 | 0 |
Shoulder dystocia | 3 | 1 (33.3%) | 0 | 1 (33.3%) | 2 (66.7%) | 1 (33.3%) | 0 |
Birth trauma | 3 | 0 | 0 | 0 | 0 | 3 (100%) | 0 |
Placental abruption | 4 | 0 | 0 | 0 | 1 (25.0%) | 3 (75.0%) | 0 |
Postpartum hemorrhage | 3 | 1 (33.3%) | 0 | 1 (33.3%) | 1 (33.3%) | 2 (66.7%) | 0 |
Anal sphincter injury | 1 | 0 | 0 | 0 | 0 | 1 (100%) | 0 |
Thrombosis | 2 | 0 | 0 | 0 | 0 | 2 (100%) | 2 (100%) |
Maternal complications of attempted VBAC | 2 | 0 | 0 | 0 | 2 (100%) | 0 | 0 |
Maternal complications of preeclampsia | 2 | 2 (100%) | 0 | 2 (100%) | 2 (100%) | 1 (50.0%) | 0 |
Combined adverse pregnancy outcome | 1 | 0 | 0 | 0 | 0 | 1 (100%) | 0 |
Short cervix | 1 | 0 | 0 | 1 (100%) | 1 (100%) | 1 (100%) | 0 |
Higher CRH levels | 1 | 0 | 0 | 1 (100%) | 0 | 1 (100%) | 0 |
For predicting preeclampsia and preterm delivery many models have been developed, but only 7.2% (5/69) and 6.3% (4/63), respectively, have been externally validated. Overall, model performance was lower at external validation than at apparent or internal validation. High discrimination (area under the receiver operating characteristic curve [AUC] >0.90) either at apparent or internal validation was observed in the development phase of 25% and 24% of models for which discrimination was presented, respectively. For preterm delivery, AUCs of models at external validation ranged between 0.65–0.72. For preeclampsia, AUCs were between 0.70–0.85 (all models for late preeclampsia). For both outcomes we found that recently developed models did not have better performance than already existing models ( Supplementary Table 2 ).
Why are existing models not yet applicable and not being used?
Despite the availability of many models for various outcomes, we are not aware of any (recent) obstetrical models that have found their way into routine practice. The reasons for this may be multiple. First, clinicians may be in doubt on whether to rely on probabilities provided by these models (ie, face validity), because models may not include well-known predictors of the outcome. Additionally, in obstetrics there tends to be an inverse relation between outcomes of mother and baby, eg, early delivery to benefit the mother might compromise baby’s outcome due to prematurity, so combining models developed on different data sets for maternal and perinatal outcomes may lower face validity. Another related issue, sometimes described as treatment paradox, can corrupt face validity when models are appropriately developed within the same data set. Predictors of the outcome or interventions that may benefit the mother but at the same time compromise the baby’s health or vice versa, leave the clinician in doubt on whether to rely on probabilities provided by these models. Second, individuals often rely on simple heuristics, ie, cognitive processes, conscious or unconscious, that ignore part of the information, which hampers incorporation of prognostic models into clinical practice. Third, prognostic models are often too complex for daily use in clinical settings without computer support (although the introduction of computerized patient records will clearly facilitate their application in routine care). Fourth, preventive treatment for the outcome that is predicted may not exist, so clinicians may prefer expectant management and treat the patient when the disease eventually develops instead of using a model. Fifth, many prognostic models have not been validated in other populations, meaning that their generalizability is unclear. And, finally, the reporting and methodological quality may be questionable or unclear, despite (recommended) methods for development of prognostic models that are well described and available in commonly used statistical software.
There are several steps to be taken between the development of a prognostic model and its use in practice. Firstly, one should question whether the implementation of a prognostic model with acceptable performance is likely to improve patient care, decision making, patient outcomes, counseling, or organization of care. Most authors of the papers identified by our systematic review described in their introduction that the possibility of accurate risk estimation for a variety of conditions would potentially have huge advantages. However, in the discussion it was usually not described how the prognostic model should be used or what was defined as being low or high risk. Secondly, a prognostic model should be developed using a sound methodological approach and its performance combined with ease of application should indicate whether the models warrants further investigation and validation. Interestingly, while reading the full-text papers, we observed that many reported that the addition of biomarkers (eg, cervical length, fetal fibronectin, serum protein levels) to characteristics of maternal and obstetric history (age, parity, previous conditions) and routine examinations (body mass index, blood pressure) often improved model discrimination up to an acceptable performance. However, if acceptable performance can be achieved with the use of only readily available variables this could make a model easier (and therefore perhaps more likely) to be used in practice. Thirdly, new or existing models should be externally validated, ideally by independent investigators, and compared to competing models, and, if necessary, updated. Less than 10% of the identified models in obstetrics have been externally validated, either in the same paper or by an independent research group. Additionally, only 164 models (62.4%) were presented in a manner for others to use, meaning that either external validation or clinical use would be possible. A fourth step after validation is to investigate whether using the prognostic model actually improves patient care: whether patient outcomes are better when changes in clinical management are made based on, or are supported by, the prognostic information provided by the model. This can be studied, for example, in a randomized trial that compares ≥1 treatment strategy guided by the prognostic model with care as usual (without the model) for relevant patient outcomes. Only 1 paper in our review discussed the issue of conducting a randomized trial to evaluate the potential clinical benefits of use of the model. For all others models, impact studies–or evidence of their initiation–were lacking. In the phase of assessing model impact it should be clear how the model should be used in practice and ideally there should be a recommendation for management of women at risks higher and lower than a certain threshold. Only a tenth of the models in this review discussed guidance for future use.
Comment
The increasing number of prognostic models for the same outcome along with the dearth of (independent) external validation studies and, more importantly, studies evaluating the clinical impact of using the prognostic model, seems to indicate that researchers in the field of obstetrics fail to appreciate the steps required in the introduction of a new prognostic model. In addition, the realization that almost 40% of papers failed to present their model in a format that could be used by others (eg, for external validation) could indicate that developers of prognostic models might not be aware of the necessity of (multiple) external validation. Furthermore, researchers seem not to critically question the consequences of developing another model along existing models for the same outcome. It has even been suggested that the increase in prognostic models can be partly attributed to the simplicity of publishing yet another paper, simply for sake of publication rather than its potential use in clinical practice. We suggest that before efforts to develop a new model are undertaken, systematic reviews should be carried out to identify and validate existing models with careful consideration to decide whether to develop a new model or update an existing model. Afterwards, the most valid, best-performing models should be studied in clinical practice in so-called impact studies to investigate influence on patient outcomes.
The usefulness of any prognostic model is predicated on full and transparent reporting of how the model was developed and validated. If key details are not reported, including the actual prognostic model (for which our review finds that 38% were insufficiently reported), then deciding whether a prognostic model has potential for practice is difficult. Systematic reviews of prognostic models in other areas of medicine have described inappropriate methodology and reporting, similar to our findings. Consensus-based guidelines have recently been published to assist authors, readers, reviewers, and journal editors on issues to report when developing or validating a prognostic model. When a model is already published, contacting the developers with a request for cooperation or additional information may help those who wish to further evaluate a model.
We have not described any assessment of the methodological conduct of the developed models and the quality of reporting of key methodological items. Although methodological quality of a model development study is–arguably–of less importance when a model shows good performance at external validation, the likelihood of developing a generalizable model (which is not overfitted to the data on which the model is developed) is higher when recommended statistical methods have been used.
Based on the large amount of prognostic modeling papers, clinicians and researchers in obstetrics seem to be open to (the use of) prognostic models, but there should be realization that it takes far more than just developing a model before patients can benefit from it. Although most authors of the papers identified by our systematic review described that accurate risk estimation would potentially have huge advantages, it remains unclear if using any of the identified models will truly impact clinical practice and contribute to improvement of patient care. Thus, at this point, we cannot recommend the routine use of any of the models. Given the potential benefits for timely prognostication and effective management, it seems unfortunate that there is such a low number of applied models. The Framingham risk score for future occurrence of cardiovascular disease, on which the decision to start preventive interventions is based, is an example of a well-studied and widely implemented prognostic model. Consequently, further investigation of model validity and impact is important and should be undertaken.
In conclusion, in obstetrics many prognostic models are developed but there is relatively little evidence about their performance, impact, and usefulness in clinical practice. New efforts in this context–or outside obstetrics–should be directed towards evaluating the performance and impact of these existing models rather than developing new ones.
Appendix
|
Publication | Outcome | Population | Study design | Women, n (events; predictors) | Type of model | Internal validation | External validation | Calibration ( P value Hosmer-Lesmeshow test or appearance calibration plot) | Discrimination (AUC) | Prediction rule | Decision recommended |
---|---|---|---|---|---|---|---|---|---|---|---|
HYPERTENSIVE DISORDERS | |||||||||||
Preeclampsia | |||||||||||
Di Lorenzo et al 2012 38 | Preeclampsia | Women with singleton pregnancies | Prospective cohort | 2218 (25; 3) | Logistic | None | None | None | None | Regression formula | No |
Khalil et al 2012 78 | Preeclampsia | Women with live singleton pregnancies | Prospective cohort | 7084 (181; unclear) | Logistic | None | None | None | 0.85 | None | No |
Myatt et al 2012 109 | Preeclampsia | Nulliparous women at low risk to develop preeclampsia | Nested case-control | 683 (174; 7) | Logistic | None | None | None | 0.73 | None | No (low sensitivity and therefore do not recommend use of model) |
Zhou et al 2012 186 | Preeclampsia | Pregnant women | Prospective cohort | 1000 (61; 5) | Logistic | None | None | None | 0.77 | None | Yes |
Hoirisch-Clapauch and Benchimol-Barbosa 2011 68 | Preeclampsia | Women with third trimester fetal loss or preterm delivery | Retrospective cohort | 133 (79; 3) | Logistic | Bootstrapping | None | None | 0.81 | Score chart | No |
North et al 2011 114 | Preeclampsia | Nulliparous women with singleton pregnancies without a recognised high risk for preeclampsia, SGA baby or spontaneous PTB | Prospective cohort | 3347 (186; 12) (model A) 3347 (186; 13) (model B) | Logistic | Crossvalidation | None | “Reasonable” (as stated in paper) | 0.71 (internal validation for models A and B) | Regression formula, probability table | Yes |
Odibo et al 2011 117 | Preeclampsia | Women with singleton pregnancies | Nested case-control | 82 (41; 7) (model A) and 82 (41; unclear) (model B) | Logistic | None | None | None | 0.82 (model A) and 0.81 (model B) | None | No |
Odibo et al 2011 118 | Preeclampsia | Women with singleton pregnancies | Prospective cohort | 452 (42; 6) | Logistic | None | None | None | 0.77 | Regression formula | No |
Seed et al 2011 156 | Preeclampsia | Women with clinical risk factors for developing preeclampsia | Randomized trial | 1121 (190; 6) (development sample) | Logistic | Split-sample | None | Fair (based on table), less in validation sample | 0.70 (development); 0.66 (validation) | Regression formula | No (performance not good enough for use in practice) |
Audibert et al 2010 16 | Preeclampsia | Nulliparous women with singleton pregnancies without major fetal anomalies | Prospective cohort | 893 (40; unclear) | Logistic | None | None | None | 0.82 | None | No |
Farina et al 2010 49 | Preeclampsia | Women who were scheduled for chorionic villous sampling or amniocentesis at 11-14 wks in which no major fetal defects were detected | Case-control | 99 (11; 4) | Logistic | None | None | None | 0.95 | None | No |
Goetzinger et al 2010 53 | Preeclampsia | Women with singleton pregnancies | Retrospective cohort | 3716 (293; 5) | Logistic | None | None | None | 0.69 | Regression formula, score chart | No |
Kenny et al 2010 77 | Preeclampsia | Healthy nulliparous women with singleton pregnancies not considered at high risk of preeclampsia, SGA or PTB due to underlying conditions | Nested case-control | 120 (60; 14) | Partial least squares–discriminant analysis | Crossvalidation and permutation testing; incorporation of validation sample for development of final model | None | None | 0.94 (discovery); 0.92 (validation) | None | No |
Sekizawa et al 2010 157 | Preeclampsia | Singleton pregnant women without any pre-existent medical diseases | Nested case-control | 372 (62; 4) | Logistic | None | None | None | 0.88 | None | No |
Phaloprakarn and Tangjitgamol 2009 127 | Preeclampsia | Women with gestational diabetes mellitus | Prospective cohort | 813 (78; 3) | Logistic | None | None | P = .79 | 0.91 | Risk score, number of risk factors vs risk | Yes |
Poon et al 2009 136 | Preeclampsia | Women with singleton pregnancies | Prospective cohort | 8051 (156; unclear) | Logistic | None | None | None | 0.81 | No | No |
Emonts et al 2008 45 | Preeclampsia | Women hospitalized with severe preeclampsia and women with a successful term delivery after a normotensive pregnancy | Unclear | 151 (101; 14) | Logistic | None | None | None | None | Regression formula | No |
Khaw et al 2008 79 | Preeclampsia | Nulliparous women with singleton pregnancies | Prospective cohort | 534 (8; 3) | Logistic | None | None | None | Only ROC curve, AUC not reported | None | No |
De Paco et al 2008 37 | Preeclampsia | Women with singleton pregnancies | Prospective cohort | 4376 (83; 5) | Logistic | None | None | None | 0.81 | Regression formula | No |
De Paco et al 2008 37 | Preeclampsia without SGA | Women with singleton pregnancies | Prospective cohort | 4376 (46; 5) | Logistic | None | None | None | 0.83 | Regression formula | No |
Poon et al 2008 133 | Preeclampsia | Pregnant women | Prospective cohort | 4619 (104; 5) | Logistic | None | None | None | 0.85 | Regression formula | No |
Plasencia et al 2007 131 | Preeclampsia | Women with singleton pregnancies | Prospective cohort | 6015 (107; 5) | Bayesian and logistic | None | None | None | 0.85 | Regression formula | No |
Papageorghiou et al 2005 121 | Preeclampsia | Unselected women with singleton pregnancies | Prospective cohort | 16806 (369; 9) | Bayesian | None | None | None | 0.79 | None | Yes |
Yu et al 2005 185 | Preeclampsia | Unselected women with singleton pregnancies | Prospective cohort | 15392 (315; 3) (development sample) | Logistic | Split sample | None | P = .76 | 0.83 (development and internal validation) | Regression formula | Yes |
August et al 2004 17 | Superimposed preeclampsia | Women with chronic hypertension | Randomized trial | 110 (37; 3) | Logistic | Jackknifing procedure | None | P = .40 | 0.69 | Probability table (no of risk factors vs risk) | No |
Mello et al 2002 107 | Preeclampsia | White normotensive pregnant women with singleton pregnancies with a history of preeclampsia | Prospective cohort | 187 (47; 8) (development sample) | Logistic | Leave-one-out method | None | None | 0.98 | None | No |
Lambert-Messerlian et al 2000 86 | Preeclampsia | Women with preeclampsia matched to controls for gestational age and date blood sampling. Women with chronic hypertension or diabetes were excluded | Case-control | 360 (60; 3) | Logistic | None | None | None | 0.75 | None | No |
Harrington et al 1997 65 | Preeclampsia | Women with singleton pregnancies | Prospective cohort | 626 (44; 7) (model A) and 626 (44; 3) (model B) | Logistic | None | None | None | Only ROC curve, AUC not reported | Regression formula | No |
Early-onset preeclampsia | |||||||||||
Abdelaziz et al 2012 10 | Early-onset preeclampsia | Women with singleton pregnancies without a priori high risk of pregnancy-induced hypertensive complications | Nested case-control | 267 (16; 3) | Logistic | None | None | None | 0.86 | None | No |
Bahado-Singh et al 2012 19 | Early-onset preeclampsia | Pregnant women attending in the first trimester | Case-control | 90 (30; 6) (model A), 90 (30; 7) (model B), 90 (30; 7) (model C), 90 (30; 9) (model D) | Logistic | None | None | None | 0.90 (model A), 0.98 (model B), 0.84 (model C), 0.94 (model D) | None | No |
Di Lorenzo et al 2012 38 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 2218 (12; 3) | Logistic None | None | None | None | 0.89 | Regression formula | No |
Akolekar et al 2011 14 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort, nested case-control | 33602 (112; 17) | Logistic | Monte Carlo simulations | None | None | Only ROC curve, AUC not reported | Algorithm on website | No |
van Kuijk et al 2011 172 | Recurrent early-onset preeclampsia | Women with early onset preeclampsia in their first singleton pregnancy (including HELLP) resulting in delivery <34 wks, having a singleton pregnancy following the index pregnancy | Retrospective cohort | 407 (28; 5) | Logistic | Bootstrapping | None | P = .11 | 0.65 (internal validation) | Regression formula | No |
Odibo et al 2011 117 | Early-onset preeclampsia | Women with singleton pregnancies | Nested case-control | 82 (unclear; 7) | Logistic | None | None | None | 0.85 | None | No |
Odibo et al 2011 118 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 452 (12; 4) | Logistic | None | None | Not reported, only “goodness of fit was evaluated” | 0.85 | Regression formula | No |
Seed et al 2011 156 | Early-onset preeclampsia | Women with clinical risk factors for developing preeclampsia | Randomized trial | 1121 (34; 5) (development sample) | Logistic | Split-sample | None | Fair (based on table), less in validation sample | 0.85 (development); 0.81 (validation) | Regression formula | No (performance not good enough for use in practice) |
Audibert et al 2010 16 | Early-onset preeclampsia | Nulliparous women with singleton pregnancies without major fetal anomalies | Prospective cohort | 893 (9; unclear) | Logistic | None | None | None | 0.99 | None | No |
Poon et al 2010 137 | Early-onset preeclampsia | Women with singleton pregnancies | Nested case-control | 402 (26; 4) | Logistic | None | None | None | 0.91 | Regression formula | No |
Poon et al 2010 138 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 8366 (37; 4) | Logistic | None | None | None | 0.79 | Regression formula | No |
Akolekar et al 2009 13 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 234 (26; 7) | Logistic | None | None | None | 0.94 | None | No |
Poon et al 2009 134 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 8366 (37; 3) | Logistic | None | None | None | 0.95 | Regression formula | No |
Poon et al 2009 135 | Early-onset preeclampsia | Women with singleton pregnancies | Nested case-control | 627 (29; 6) | Logistic | None | None | None | Only ROC curves, AUC not reported | Regression formula | No |
Poon et al 2009 136 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 8051 (32; 5) | Logistic | None | None | None | 0.91 | Regression formula, risk table | Yes |
Akolekar et al 2008 12 | Early-onset preeclampsia | Pregnant women attending for routine assessment | Case-control | 824 (29; 5) | Logistic | None | None | None | 0.94 | Regression formula | No |
Onwudiwe et al 2008 120 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 2829 (23; 3) | Logistic | None | None | None | 0.996 | Regression formula | No |
Plasencia et al 2008 132 | Early-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 3107 (22; 5) | Logistic | None | None | None | 0.98 | Regression formula | No |
Yu et al 2005 185 | Early-onset preeclampsia | Unselected women with singleton pregnancies | Prospective cohort | 15392 (72; 3) (development sample) | Logistic | Split-sample | None | P = .98 | 0.95 (development and internal validation) | Regression formula | Yes |
Masse et al 1993 103 | Early-onset preeclampsia | Nulliparous women | Prospective cohort | 1366 (109; 9) (model A), 1366 (109; 5) (model B), 1366 (109; 11) (model C) and 1366 (109; 7) (model D) | Logistic | None | None | None | None | Regression formula | No |
Intermediate-onset preeclampsia | |||||||||||
Akolekar et al 2011 14 | Intermediate-onset preeclampsia | Women with singleton pregnancies | Prospective cohort, nested case-control | 33602 (187; 17) | Logistic | Monte Carlo simulations | None | None | Only ROC curve, AUC not reported | Algorithm on website | No |
Late-onset preeclampsia | |||||||||||
Abdelaziz et al 2012 10 | Late-onset preeclampsia | Women with singleton pregnancies without a priori high risk of pregnancy-induced hypertensive complications | Nested case-control | 267 (60; 3) | Logistic | None | None | None | 0.83 | None | No |
Larsen et al 2012 87 | Postpartum preeclampsia | women readmitted in postpartum period with late postpartum preeclampsia and controls that delivered closely before/after case | Case-control | 153 (51; 4) | Logistic | None | None | None | 0.90 | None | No |
Akolekar et al 2011 14 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort, nested case-control | 33602 (453; 17) | Logistic | Monte Carlo simulations | None | None | Only ROC curve, AUC not reported | Algorithm on website | No |
Youssef et al 2011 184 | Late-onset preeclampsia | Pregnant women attending a tertiary level center | Prospective cohort | 528 (13; 3) | Logistic | None | None | None | 0.82 | Risk groups | No |
Ashoor 2010 15 | Late-onset preeclampsia | Women with singleton pregnancies without a history of thyroid disease | Prospective cohort | 3694 (77; 9) | Logistic | None | None | None | 0.86 | None | No |
Poon et al 2010 137 | Late-onset preeclampsia | Women with singleton pregnancies | Nested case-control | 402 (90; 5) (model A) and 402 (90; 4) (model B) | Logistic | None | None | None | 0.88 (model A); 0.86 (model B) | Regression formula | No |
Poon et al 2010 138 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 8366 (128; 5) | Logistic | None | None | None | 0.80 | Regression formula | No |
Akolekar et al 2009 13 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 303 (95; 5) | Logistic | None | None | None | 0.83 | None | No |
Poon et al 2009 134 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 8366 (128; 3) | Logistic | None | None | None | 0.86 | Regression formula | No |
Poon et al 2009 135 | Late-onset preeclampsia | Women with singleton pregnancies | Nested case-control | 627 (89; 6) | Logistic | None | By Farina et al, 2011 | None | Only ROC curves, AUC not reported (development); 0.74-0.75 (external validation) | Regression formula | No |
Poon et al 2009 136 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 8051 (124; 5) | Logistic | None | By Farina et al, 2011 | None | 0.79 (development); 0.70 (external validation) | Regression formula | No |
Akolekar et al 2008 12 | Late-onset preeclampsia | Pregnant women attending for routine assessment | Case-control | 824 (98; 6) | Logistic | None | None | None | 0.817 | Regression formula | No |
Onwudiwe et al 2008 120 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 2884 (78; 5) | Logistic | None | By Farina et al, 2011 | None | 0.83 (development); 0.85 (external validation) | Regression formula | No |
Plasencia et al 2008 132 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 3107 (71; 6) (model A); 3107 (71; 7 (model B) | Logistic | None | By Farina et al, 2011 | None | 0.78 (model A); 0.78 (model B) 0.76 on external validation | Regression formula | No |
Plasencia et al 2007 131 | Late-onset preeclampsia | Women with singleton pregnancies | Prospective cohort | 6015 (unclear; 4) | Bayesian and logistic | None | By Farina et al, 2011 and by Herraiz et al, 2009 | None | 0.84 (development); 0.72 (external validation by Farina); 0.64 (external validation by Herraiz) | Regression formula | No |
Yu et al 2005 185 | Late-onset preeclampsia | Unselected women with singleton pregnancies | Prospective cohort | 15392 (243; 3) (development sample) | Logistic | Split-sample | None | P = .83 | 0.80 (development and internal validation) | Regression formula | Yes |
Severe preeclampsia | |||||||||||
Myatt et al 2012 109 | Severe preeclampsia (including eclampsia and HELLP syndrome) | Nulliparous women at low risk to develop preeclampsia | Nested case-control | 683 (72; 5) | Logistic | None | None | None | 0.75 | None | No (low sensitivity and therefore do not recommend use of model) |
Audibert et al 2010 16 | Severe preeclampsia | Nulliparous women with singleton pregnancies without major fetal anomalies | Prospective cohort | 893 (16; unclear) | Logistic | None | None | None | 0.89 | None | No |
Lee et al 2000 92 | Severe preeclampsia | Women with singleton pregnancies | Retrospective cohort | 1052 (56; 4) | Logistic | None | None | None | 0.77 | Risk score | No |
Stamilio et al 2000 164 | Severe preeclampsia | Women with singleton pregnancies | Retrospective cohort | 1998 (49; 4) | Logistic | None | None | “good fit,” statistics not reported | 0.75 | Risk score | Yes |
Eclampsia | |||||||||||
Koopmans et al 2011 83 | Eclampsia | Women with mild PE or PIH ≥36 wks (controls) and women who developed eclampsia >36 wks (cases) | Nested case-control | 1225 (76; 12) | Logistic | Bootstrapping | None | None | 0.92 (development); 0.88-0.89 (internal validation) | None | No |
Gestational hypertension | |||||||||||
Abdelaziz et al 2012 10 | Gestational hypertension | Women with singleton pregnancies without a priori high risk of pregnancy-induced hypertensive complications | Nested case-control | 267 (13; 3) | Logistic | None | None | None | 0.73 | None | No |
Di Lorenzo et al 2012 38 | Gestational hypertension | Women with singleton pregnancies | Prospective cohort | 2218 (46; 4) | Logistic | None | None | None | None | Regression formula | No |
Khalil et al 2012 78 | Gestational hypertension | Women with live singleton pregnancies | Prospective cohort | 7084 (137; unclear) | Logistic | None | None | None | 0.85 | None | No |
Poon et al 2010 137 | Gestational hypertension | Women with singleton pregnancies | Nested case-control | 402 (85; 3) | Logistic | None | None | None | 0.72 | Regression formula | No |
Poon et al 2010 138 | Gestational hypertension | Women with singleton pregnancies | Prospective cohort | 8366 (140; 4) | Logistic | None | None | None | 0.72 | Regression formula | No |
Poon et al 2009 134 | Gestational hypertension | Women with singleton pregnancies | Prospective cohort | 8366 (140; 3) | Logistic | None | None | None | 0.79 | Regression formula | No |
Poon et al 2009 135 | Gestational hypertension | Women with singleton pregnancies | Nested case-control | 627 (82; 4) | Logistic | None | None | None | Only ROC curves, AUC not reported | Regression formula | No |
Onwudiwe et al 2008 120 | Gestational hypertension | Women with singleton pregnancies | Prospective cohort | 2880 (74; 5) | Logistic | None | None | None | 0.84 | Regression formula | No |
Plasencia et al 2007 131 | Gestational hypertension | Women with singleton pregnancies | Prospective cohort | 6015 (107; 3) | Bayesian and logistic | None | None | None | 0.71 | Regression formula | No |
Tomoda et al 1996 168 | Gestational hypertension | Nulliparous women that delivered a singleton without major anomalies after 32 wks | Retrospective cohort | 1189 (305; 4) | Linear regression (4 grades of hypertension as continuous variable) | None | None | None | None | Regression formula | No |
Tomoda et al 1996 168 | Gestational hypertension | Multiparous women that delivered a singleton without major anomalies after 32 wks | Retrospective cohort | 957 (192; 4) | Linear regression (4 grades of hypertension as continuous variable) | None | None | None | None | Regression formula | No |
PRETERM DELIVERY | |||||||||||
Preterm delivery <28 wks in asymptomatic women | |||||||||||
Celik et al 2008 32 | Preterm delivery <28 wks | Women attending for routine care | Prospective cohort | 58807 (139; 3) | Logistic | None | None | P = .49 | 0.90 | Regression formula | No |
Preterm delivery <30 wks in asymptomatic women | |||||||||||
Celik et al 2008 32 | Preterm delivery 28-30 wks | Women attending for routine care | Prospective cohort | 58807 (215; 3) | Logistic | None | None | P = .97 | 0.82 | Regression formula | No |
Preterm delivery <32 wks in asymptomatic women | |||||||||||
Fuchs et al 2012 50 | Preterm delivery <32 wks | Women with a singleton pregnancy receiving emergency cervical cerclage | Retrospective cohort | 85 (37; 4) | Logistic | None | None | None | 0.85 (0.88 for score chart) | Score chart | No |
Lee et al 2011 91 | Preterm delivery <32 wks | Asymptomatic women who delivered singleton live newborns at ≥24 wks of gestation | Prospective cohort | 522 (14; 13) (total sample) | Bayesian | Split-sample | None | None | None | None | No |
Tan et al 2007 165 | Preterm delivery <32 wks | Women with singleton pregnancies | Retrospective cohort | 2391480 (unclear; 9) (development sample) | Logistic | Split-sample | None | None | 0.73 | Regression formula | No |
Tan et al 2007 165 | Preterm delivery <32 wks | Women with twin pregnancies | Retrospective cohort | 83673 (unclear; 9) (development sample) | Logistic | Split-sample | None | None | 0.65 | Regression formula | No |
Tan et al 2007 165 | Preterm delivery <32 wks | Women with triplet pregnancies | Retrospective cohort | 3110 (unclear; 9) (development sample) | Logistic | Split-sample | None | None | 0.65 | Regression formula | No |
To et al 2006 167 | Preterm delivery <32 wks | Women with singleton pregnancies | Prospective cohort | 40995 (223; 7) | Logistic | None | None | None | 0.67 | Regression formula, probability table | Yes |
Odibo et al 2003 115 | Spontaneous preterm delivery <32 wks | High-risk patients who received cerclage at 10-24 wks based on history | Retrospective cohort | 256 (51; 3) | Logistic | None | None | None | 0.91 | Score chart | Yes |
Preterm delivery <32 wks in asymptomatic women | |||||||||||
Goldenberg et al 2001 54 | Spontaneous preterm delivery <32 wks | Asymptomatic women with singleton pregnancies with ≤3 cm (multiparous women) or ≤2 com (nulliparous women) cervix dilation | Nested case-control | 100 (50; 6) | Logistic | None | None | None | None (authors feel this is not appropriate because of case-control design) | None | No |
Preterm delivery <34 wks in asymptomatic women | |||||||||||
Greco et al 2012 58 | Preterm delivery <34 wks | Women with singleton pregnancies | Prospective cohort | 9974 (104; 5) | Logistic | None | None | None | 0.84 | None | No |
Kiefer et al 2012 80 | Preterm delivery <34 wks (with a score for amniotic inflammation) | Women with singleton pregnancies with risk factors for PTB | Prospective cohort | 44 (unclear; 14) | None (univariable analysis only) | None | In same paper | None | None | Score chart (for amniotic inflammation) | No |
Beta et al 2011 24 | Spontaneous preterm delivery <34 wks | Women with singleton pregnancies | Prospective cohort, nested case-control | 33370 (353; 6) | Logistic | None | None | None | 0.67 | None | No |
Lee et al 2011 91 | Preterm delivery <34 wks | Asymptomatic women who delivered singleton live newborns at ≥24 wks of gestation | Prospective cohort | 522 (28; 13) (total sample) | Bayesian | Split-sample | None | None | None | None | No |
Celik et al 2008 32 | Preterm delivery 31-33 wks | Women attending for routine care | Prospective cohort | 58807 (526; 3) | Logistic | None | None | P = .20 | 0.78 | Regression formula | No |
Preterm delivery <35 wks in asymptomatic women | |||||||||||
de Oliveira et al 2012 36 | Spontaneous preterm delivery <35 wks | Women with singleton pregnancy between 22 and 34 wks of gestation | Prospective cohort | 70 (unclear; 9) | Logistic | Bootstrapping | None | None | 0.91 | Probability table | No |
Preterm delivery <35 wks in asymptomatic women | |||||||||||
Esplin et al 2011 46 | Preterm delivery <35 wks | Asymptomatic pregnant women | Nested case-control | 160 (80; 3) | Logistic | None | None | None | 0.89 | None | No |
Goldenberg et al 2001 54 | Spontaneous preterm delivery <35 wks | Asymptomatic women with singleton pregnancies with ≤3 cm (multiparous women) or ≤2 com (nulliparous women) cervix dilation | Nested case-control | 254 (127; 7) | Logistic | None | None | None | None (authors feel this is not appropriate because of case-control design) | None | No |
Preterm delivery <36 wks in asymptomatic women | |||||||||||
Celik et al 2008 32 | Preterm delivery 34-36 wks | Women attending for routine care | Prospective cohort | 58807 (2356; 3) | Logistic | None | None | P = .20 | 0.62 | Regression formula | No |
Grzymala-Busse and Woolery 1994 62 | Preterm delivery <36 wks | Unclear | Unclear | 9480 (unclear; unclear) (development sample) | Logistic, machine learning | Split-sample | None | None | None | None | No |
Preterm delivery <37 wks in asymptomatic women | |||||||||||
Greco et al 2012 58 | Preterm delivery 34-36 wks | Women with singleton pregnancies | Prospective cohort | 9974 (213; 5) | Logistic | None | None | None | 0.58 | None | No |
Elaveyini et al 2011 44 | Preterm delivery <37 wks | Women with a pregnancy complicated by first-trimester intrauterine hematoma | Retrospective cohort | 50 (6; unclear) (total sample) | Artificial neural network | Split-sample | None | None | None | None | No |
Goodwin et al 2001 57 | Preterm delivery <37 wks | Ethnically diverse sample of pregnant women | Retrospective cohort | 19970 (4433; 7) | An experimental classifier software program based on statistical, case-based, and CART algorithms, using only demographic variables | None | None | None | 0.72 | None | No |
Lee et al 2011 91 | Preterm delivery <37 wks | Asymptomatic women who delivered singleton live newborns at ≥24 wks of gestation | Prospective cohort | 522 (96; 13) (total sample) | Bayesian | Split-sample | None | None | None | None | No |
van Ravenswaaij et al 2011 174 | Spontaneous preterm delivery 16-37 wks | Women who underwent first trimester screening | Retrospective cohort | 28566 (1503; 4) | Logistic | None | None | None | 0.65 | Regression formula | No |
Pearce et al 2010 125 | Idiopathic preterm delivery <37 wks | Pregnant women | Nested case-control | 183 (60; 6) | Logistic | None | None | None | 3 top ranked models 0.81; 0.78; 0.75 | None | No |
Esplin et al 2008 45 | Preterm delivery <34 and <37 wks | Women with a first live birth and at least one subsequent live birth | Retrospective cohort | 98724 (395; 20) | Multinomial regression | None | In same paper | None | 0.72 (in validation sample) | None | No |
Catley et al 2006 31 | Preterm delivery <37 wks | Births in the Canadian province of Ontario | Retrospective cohort | 48000 (4128; 8) | Artificial neural network | None | In same paper | None | 0.65 | None | No |
Catley et al 2006 31 | “High-risk preterm delivery” (delivery <33 wks or delivery 33-36 wks with low Apgar score, low birthweight, NICU admission and/or neonatal resuscitation) | Births in the Canadian province of Ontario | Retrospective cohort | 10864 (2173; 7) | Artificial neural network | None | In same paper | None | 0.71 | None | No |
Smith et al 2006 159 | Preterm delivery <37 wks | Women having first pregnancies in West of Scotland | Retrospective cohort | 84391 (5275; 10) | Logistic | None | None | None | 0.67 for delivery 24-28 wks, 0.65 for delivery 29-32 wks, and 0.62 for delivery 33-36 wks | None | No |
Onderdonk et al 2003 119 | Preterm delivery <37 wks | Women with a previous preterm delivery | Prospective cohort | 32 (11; 7) | Logistic | None | None | None | 0.82 | Regression formula | Yes |
Onderdonk et al 2003 119 | Preterm delivery <37 wks | Women with a previous preterm delivery and without vaginal bleeding | Prospective cohort | 28 (9; 4) | Logistic | None | None | None | 0.91 | Regression formula | Yes |
Onderdonk et al 2003 119 | Preterm delivery <37 wks | Women without a previous preterm birth with H2O2 positive lactobacilli present | Prospective cohort | 139 (15; 6) | Logistic | None | None | None | 0.74 | Regression formula | Yes |
Onderdonk et al 2003 119 | Preterm delivery <37 wks | Women without a previous PTB with H2O2 positive lactobacilli absent | Prospective cohort | 35 (2; 3) | Logistic | None | None | None | 0.94 | Regression formula | Yes |
Mara et al 2002 102 | Preterm delivery <37 wks | Unselected women with singleton pregnancies without fetal anomalies | Prospective cohort | 314 (38; 5) | Logistic | None | None | None | None | None | No |
Ruiz et al 2002 152 | Gestational age at delivery (preterm delivery defined as <37 wks) | Women with singleton pregnancies | Prospective cohort | 76 (6; 4) | Linear regression | None | None | None | None | None | No |
McLean et al 1999 105 | Preterm delivery <37 wks | unselected pregnant women who did not use systemic corticosteroids | Prospective cohort | 819 (unclear; 3) | Bayesian | None | None | None | Only ROC curve, AUC not reported | Risk groups and risk | No |
Mercer et al 1996 108 | Spontaneous preterm delivery <37 wks | Nulliparous women with singleton pregnancies | Prospective cohort | 1218 (100; 7) (total sample) | Logistic | Split-sample | None | None | None | Regression formula | No |
Mercer et al 1996 108 | Spontaneous preterm delivery <37 wks | Multiparous women with singleton pregnancies | Prospective cohort | 1711 (204; 4) (total sample) | Logistic | Split-sample | None | None | None | Regression formula | No |
de Caunes et al 1990 35 | Preterm delivery <37 wks | Singleton deliveries | Case-control | 746 (unclear; 9) (total sample) | Unclear | Split-sample | None | Calibration plot: no clear interpretation | None | Score chart | No |
Blondel et al 1990 27 | Preterm delivery <37 wks | Nulliparous women with singleton pregnancies | Retrospective cohort | 4025 (201; 9) | Logistic | None | None | None | None | Regression formula | No |
Blondel et al 1990 27 | Preterm delivery <37 wks | Multiparous women with singleton pregnancies | Retrospective cohort | 2884 (153; 9) | Logistic | None | None | None | None | Regression formula | No |
Ross et al 1986 151 | Preterm delivery <37 wks | Pregnant women | Retrospective cohort | 8240 (530; 22) | Unclear | None | None | None | None | Regression formula, score chart | No |
Bouyer et al 1986 28 | Preterm delivery <37 wks | Nulliparous women with singleton pregnancies | Prospective cohort | 2046 (121; 8) | Logistic | None | None | None | None | Regression formula | No |
Bouyer et al 1986 28 | Preterm delivery <37 wks | Multiparous women with singleton pregnancies | Prospective cohort | 2344 (129; 10) | Logistic | None | None | None | None | Regression formula | No |
Guzick et al 1984 64 | Preterm delivery <37 wks | Pregnant women | Unclear | 2865 (254; 7) | Logistic | None | None | None | None | Regression formula | No |
Preterm delivery <34 wks in symptomatic women | |||||||||||
Vogel et al 2005 175 | Preterm delivery <34 wks | Women with singletons who had spontaneous contractions, PPROM or cervical ripening between 24 and 33+6 wks | Prospective cohort | 93 (46; 3) | Logistic | None | None | None | 0.91 | None | No |
Preterm delivery <37 wks in symptomatic women | |||||||||||
Bastek et al 2012 20 | Preterm delivery <37 wks | Women with a singleton pregnancy at 22-34 wks with symptoms of preterm labor | Prospective cohort | 583 (204; 3) | Logistic | Bootstrapping | None | None | 0.73 (0.72 for score chart) | Score chart | No |
Kurkinen-Raty et al 2001 85 | Spontaneous preterm delivery <37 wks | Women with singleton pregnancies at 22-32 wks of gestation with symptoms or signs of threatened PTB (but not ruptured membranes), and symptomless women matched for gestational age, parity and maternal age | Case-control | 155 (14; 3) | Logistic | None | None | None | None | None | No |
Nicholson et al 2001 113 | Preterm delivery <37 wks | Women between 24 and 34 wks’ gestation who were admitted with idiopathic preterm labor (without concomitant premature rupture of membranes) and treated with tocolysis | Retrospective cohort | 900 (247; 3) | Logistic | None | None | None | None | None | No |
Hueston 1998 70 | Preterm delivery <37 wks | Women with preterm contractions in level I and level II facilities | Retrospective cohort | 239 (78; 4) | Logistic | None | None | None | None | None | No |
Woolery and Grzymala-Busse 1995 183 | Preterm delivery <37 wks | High- and low-risk pregnant women in a level III perinatal center | Unclear | 9480 (unclear; unclear) (development sample) | Logistic, machine learning | Split- sample | None | None | None | None | No |
Preterm delivery <48 hrs in symptomatic women | |||||||||||
Park et al 2011 122 | Preterm delivery <48 hrs | Women diagnosed with PPROM with live singleton with gestational age 23-34, dilatation <3 cm | Prospective cohort | 102 (24; 3) (model A) and 102 (24; 3) (model B) | Logistic | None | None | P = .18 (model A) and P = .11 (model B) | 0.80 (model A) and 0.83 (model B) | Regression formula | No |
Macones et al 1999 98 | Preterm delivery <48 hrs | Women with idiopathic preterm labor without ruptured membranes and treated with magnesium sulfate between 24 and 34 completed wks of gestation | Case-control | 200 (50; 6) | Logistic | None | None | None | None | None | No |
Besinger et al 1987 23 | Preterm delivery <48 hrs | Women with preterm labor pregnant between 26 and 34 wks of gestation | Prospective cohort | 50 (20; 3) (model A), 50 (20; 4) model B. 50 (20; 5) model C | Logistic | None | None | None | None | None | No |
Preterm delivery <7 days in symptomatic women | |||||||||||
Giannella et al 2012 52 | Delivery within 7 days | Women with spontaneous preterm labor between 24 and 34 wks | Prospective cohort | 730 (110; 3) | Logistic | None | None | None | 0.95 | None | No |
Tsiartas et al 2012 169 | Delivery within 7 days | Women with a singleton pregnancy with threatened preterm labor between 22-34 wks | Prospective cohort | 142 (57; 3) | Logistic | None | None | P = .91 | 0.88 | Regression formula | No |
Park et al 2011 122 | Delivery within 7 days | Women diagnosed with PPROM with live singleton with gestational age 23-34, dilatation <3 cm | Prospective cohort | 91 (51; 3) | Logistic | None | None | None | 0.77 | Regression formula | No |
Holst et al 2009 69 | Spontaneous preterm delivery within 7 days | Healthy women with singleton pregnancies who were in preterm labor (22-33 wks) with intact membranes | Prospective cohort | 89 (34; 4) (model A) and 89 (34; 3) (model B) | Logistic | None | None | None | 0.91 (model A); 0.91 (model B) | None | No |
Macones et al 1999 96 | Preterm delivery within 7 days | Women between 24 and 34 wks’ gestation who sought treatment for uterine contractions with cervical dilatation ≤2 cm, received tocolysis with magnesium sulfate, without spontaneous rupture of membranes on admission | Case-control | 200 (50; 3) | Logistic | None | None | None | None | None | No (“because of the modest performance we do not believe that our clinical rule could be used alone”) |
Hueston 1998 70 | Preterm delivery within 7 days (and <34 wks) | Women with preterm contractions in level I and level II facilities | Retrospective cohort | 239 (26; 5) | Logistic | None | None | None | None | None | Yes |
Faber et al 1995 48 | Delivery within 7 days | Women with preterm labor | Prospective cohort | 114 (unclear; 5) | Logistic | None | None | None | None | Regression formula | No |
Preterm delivery <10 days in symptomatic women | |||||||||||
Bastek et al 2012 20 | Delivery within 10 days | Women with a singleton pregnancy at 22-33+6/7 wks with symptoms of preterm labor | Prospective cohort | 583 (90; 3) | Logistic | Bootstrapping | None | None | 0.75 (0.76 for score chart) | Score chart | No |
GESTATIONAL DIABETES | |||||||||||
Gestational diabetes | |||||||||||
Ramos-Levi et al 2012 141 | Gestational diabetes mellitus | Women without a previous history of diabetes mellitus | Cross-sectional cohort | 2194 (213; 6) | Logistic | None | None | None | None | Regression formula | No |
Zhou et al 2012 186 | Gestational diabetes mellitus | Pregnant women | Prospective cohort | 1000 (100; 5) | Logistic | None | None | None | 0.71 | None | Yes |
Nanda et al 2011 111 | Gestational diabetes mellitus | Women without pre-pregnancy diabetes mellitus type 1 or 2 with singleton pregnancies delivering a phenotypically normal neonate at or after 30 wks of gestation, attending for their routine first hospital visit | Prospective cohort, nested case-control | 11464 (297; 6) | Logistic | None | None | None | 0.84 | None | No |
Nanda et al 2011 111 | Gestational diabetes mellitus | Women with previous gestational diabetes but without pre-pregnancy diabetes mellitus type 1 or 2 with singleton pregnancies delivering a phenotypically normal neonate at or after 30 wks of gestation, attending for their routine first hospital visit | Prospective cohort, nested case-control | 107 (63; 6) | Logistic | None | None | None | 0.87 | None | No |
Nanda et al 2011 111 | Gestational diabetes mellitus | Women without previous gestational diabetes and without pre-pregnancy diabetes mellitus type 1 or 2 with singleton pregnancies delivering a phenotypically normal neonate at or after 30 wks of gestation, attending for their routine first hospital visit | Prospective cohort, nested case-control | 11357 (234; 6) | Logistic | None | None | None | 0.81 | None | No |
Teede et al 2011 166 | Gestational diabetes mellitus | Women with singleton pregnancies | Retrospective cohort | 2880 (250; 5) | Logistic | None | In same paper | None | 0.70 (external validation) | Score chart | No |
Savvidou et al 2010 153 | Gestational diabetes mellitus | Women with singleton pregnancies, without pre-existing diabetes mellitus | Nested case-control | 372 (124; 11) (model A) and 372 (124; 5) (model B) | Logistic | Bootstrapping | None | None | 0.82 (model A) and 0.86 (model B) | None | No |
Savvidou et al 2010 153 | Gestational diabetes mellitus | Women with singleton pregnancies, without pre-existing diabetes mellitus or previous gestational diabetes | Nested case-control | 202 (44; 11) (model A) and 202 (44; 5) (model B) | Logistic | Bootstrapping | None | None | 0.75 (model A) and 0.81 (model B) | None | No |
van Leeuwen et al 2010 173 | Gestational diabetes mellitus | Women with singleton pregnancies without pregestational diabetes mellitus | Prospective cohort | 995 (24; 5) | Logistic | None | None | P = .25 | 0.77 | Regression formula, nomogram | Yes |
Insulin treatment for gestational diabetes | |||||||||||
Pertot et al 2011 126 | Need for insulin treatment in gestational diabetes mellitus | Women with gestational diabetes mellitus | Prospective cohort | 3009 (1535; 7) | Logistic | None | None | Calibration table: good calibration | None | None | No |
Abnormal glucose challenge test | |||||||||||
Phaloprakarn et al 2009 128 | Abnormal glucose challenge test | Singleton pregnant women without overt diabetes | Retrospective cohort | 1876 (586; 5) | Logistic | None | In same paper | None | 0.80 (development); 0.75 (validation) | Prognostic index | No |
Congenital malformations | |||||||||||
Garcia-Patterson et al 2004 51 | Any major congenital malformations (≥1) | Infants of mothers with gestational diabetes | Prospective cohort | 983 (unclear; 3) | Logistic | None | None | None | 0.65 | None | No |
Garcia-Patterson et al 2004 51 | Any minor congenital malformations (≥1) | Infants of mothers with gestational diabetes | Prospective cohort | 983 (unclear; 3) | Logistic | None | None | None | 0.60 | None | No |
Garcia-Patterson et al 2004 51 | Major congenital malformations of the heart | Infants of mothers with gestational diabetes | Prospective cohort | 983 (unclear; 4) | Logistic | None | None | None | 0.81 | None | No |
FETAL GROWTH AND WEIGHT | |||||||||||
Small for gestational age neonate | |||||||||||
Karagiannis et al 2011 75 | SGA neonate in absence of preeclampsia | Women with singleton pregnancies who did not develop preeclampsia | Prospective cohort, nested case-control | 32850 (1536; unclear) | Logistic | Monte Carlo simulations | None | None | Only ROC curve, AUC not reported | None | No |
Karagiannis et al 2011 75 | SGA neonate in absence of preeclampsia with delivery indicated <37 wks | Women with singleton pregnancies who did not develop preeclampsia | Prospective cohort, nested case-control | 32850 (163; unclear) | Logistic | Unclear | None | None | None | None | No |
Karagiannis et al 2011 75 | SGA neonate in absence of preeclampsia with delivery >37 wks | Women with singleton pregnancies who did not develop preeclampsia | Prospective cohort, nested case-control | 32850 (1373; unclear) | Logistic | Unclear | None | None | None | None | No |
Poon et al 2011 139 | SGA neonate in absence of preeclampsia | Women with singleton pregnancies who did not develop preeclampsia | Prospective cohort | 32850 (1536; 11) | Logistic | None | None | None | 0.75 | Risk curve | No |
Seed et al 2011 156 | SGA neonate | Women with clinical risk factors for developing preeclampsia | Randomized trial | 1121 (255; 6) (development sample) | Logistic | Split-sample | None | Fair (based on table), less in validation sample | 0.65 (development); 0.57 (validation) | Regression formula | No (performance not good enough for use in practice) |
Seed et al 2011 156 | SGA neonate with severe adverse perinatal outcome | Women with clinical risk factors for developing preeclampsia | Randomized trial | 1121 (104; 4) (development sample) | Logistic | Split-sample | None | Fair (based on table), less in validation sample | 0.73 (development); 0.66 (validation) | Regression formula | No (performance not good enough for use in practice) |
Onwudiwe et al 2008 120 | SGA neonate | Women with singleton pregnancies | Prospective cohort | 3172 (366; 5) | Logistic | None | None | None | 0.65 | Regression formula | No |
De Paco et al 2008 37 | SGA neonate | Women with singleton pregnancies | Prospective cohort | 4376 (532; 5) | Logistic | None | None | None | 0.63 | None | No |
Pilalis et al 2007 129 | SGA neonate | Women with singleton pregnancies | Prospective cohort | 878 (94; 4) | Logistic | None | None | None | None | None | No |
Plasencia et al 2007 131 | SGA neonate | Women with singleton pregnancies | Prospective cohort | 6015 (760; 7) | Bayesian and logistic | None | None | None | 0.66 | Regression formula | No |
Intrauterine growth restriction | |||||||||||
Bachman et al 2003 18 | IUGR | Women with singleton pregnancies | Prospective cohort | 260 (22; 3) | Logistic | None | None | None | 0.83 | Number of risk factors vs risk | No |
Doherty et al 2002 41 | IUGR (birthweight <p10) | Sample of unselected pregnancies with oversampling of cases with abnormal outcomes | Randomized controlled trial | 114 (43; 4) (model A); 114 (43; 7) (model B) (development sample) | None | Split-sample | None | None | Only ROC curve, AUC not reported | Regression formula | No |
de Caunes et al 1990 35 | IUGR | Singleton deliveries | Case-control | 746 (unclear; 12) (total sample) | Unclear | Split-sample | None | Calibration plot: no clear interpretation | None | Score chart | No |
Snidvongs et al 1989 161 | IUGR | Pregnant women | Prospective cohort | 766 (71; 6) | Logistic | None | None | None | Only ROC curve, AUC not reported | Score chart | Yes |
Birthweight | |||||||||||
Liu et al 2008 96 | Birthweight | Women with preeclampsia or gestational hypertension | Retrospective cohort | 661 (NA; 6) (model A) and 661 (NA; 5) (model B) | Linear regression | None | In same paper | None | 0.94 (model A); 0.78 (model B); when cutoff of 2555 g was used | Regression formula | No |
Mamelle et al 2001 101 | Individualized birthweight limit of an infant (taking into account genetic growth potential, in order to distinguish ‘fetal growth-restricted’ infants and ‘constitutionally small’ infants) | Liveborn singletons in maternity hospitals located in various regions of France and in Belgium | Retrospective cohort | 71778 (NA; 6) | Linear regression | None | None | None | None | Regression formula | Yes |
Weiner et al 1985 178 | Birthweight | Pregnant women likely to deliver preterm (<34 wks) within 48 hrs | Prospective cohort | 33 (NA; 3) (development sample) | Linear regression | Split-sample | By Pielet et al, 1987 | None | None | Regression formula | No |
Low birthweight | |||||||||||
de Caunes et al 1990 35 | Low birthweight | Women with singleton deliveries | Case-control | 746 (unclear; 10) (total sample) | Unclear | Split-sample | None | Calibration plot: no clear interpretation | None | Score chart | No |
LABOR AND DELIVERY | |||||||||||
Vaginal birth after cesarean | |||||||||||
Grobman et al 2009 60 | VBAC | Women who underwent a trial of labor at ≥37 wks with 1 previous low-transverse cesarean and vertex singleton | Retrospective cohort | 9616 (7066; 12) (total sample) | Logistic | Split-sample | By Costantine et al, 2011 | “Adequate” based on calibration plot Adequate on external validation | 0.77 0.76 on external validation | Regression formula, nomogram | No |
Grobman et al 2007 59 | VBAC | Women with one prior low transverse cesarean who underwent a trial of labor at term with a vertex singleton gestation | Prospective cohort | 11856 (8659; 6) (total sample) | Logistic | Split-sample | By Costantine et al, 2009 | None Fair on external validation (curve) | 0.75 (for formula and nomogram in internal validation sample) 0.70 on external validation | Regression formula, nomogram | No |
Hashima and Guise 2007 66 | VBAC | Primiparous women with 1 prior cesarean | Retrospective cohort | 10828 (unclear; 3) (total sample) | Logistic | Split-sample | None | None | None | Scoring system | No |
Srinivas et al 2007 163 | VBAC | Women with a previous cesarean delivery | Retrospective cohort | 13706 (10340; 6) | Logistic | None | None | None | 0.72 | None | No |
Kraiem et al 2006 84 | VBAC | Women with a prior uterine scar (cesarean or myomectomy) | Retrospective cohort | 581 (268; 5) | Logistic | None | None | None | None | Score chart | No |
Smith et al 2005 158 | Failed VBAC (emergency cesarean) | Women with singletons with one prior cesarean delivery who attempted vaginal birth at or after 40 wks of gestation | Retrospective cohort | 11643 (3067; 6) (development sample) | Logistic | Split sample | None | P = .95 | 0.71 | Regression formula | No |
Gonen et al 2004 56 | VBAC | Women with history of 1 low tranverse cesarean delivery | Retrospective cohort | 339 (279; 4) | Logistic | None | None | None | None | None | No |
Weinstein et al 1996 179 | VBAC | Women with a prior cesarean who attempted vaginal birth | Retrospective cohort | 471 (368; 4) | Logistic | None | None | None | None | Score chart | No |
Jakobi et al 1993 72 | VBAC | Women with a previous cesarean who were allowed to trial of labor | Unclear | 261 (147; 6) | Logistic | None | None | None | None | None | No |
Induction of labor | |||||||||||
Rao et al 2008 145 | Induction of labor | Singleton pregnancies with a live fetus at 40+4 to 41+6 wks of gestation | Prospective cohort | 1864 (328; 4) | Logistic | None | None | None | 0.76 | Regression formula | No |
Vaginal delivery within 24 hrs after induction of labor | |||||||||||
Pitarello et al 2013 130 | Successful vaginal delivery within 24 hrs | Women with singleton live term fetus in cephalic presentation | Prospective cohort | 190 (119; 4) | Logistic | None | None | None | 0.81 | Regression formula | No |
Mbele et al 2007 104 | Successful vaginal delivery within 24 hrs | Women with singleton pregnancy who underwent an induction of labor with oral misoprostol | Prospective cohort | 558 (53; 4) | Logistic | None | None | None | None | Scoring system | No |
Bueno et al 2007 30 | Successful vaginal delivery within 24 hrs | Women admitted for induction of labor | Unclear | 196 (144; 5) | Logistic | None | None | None | None | None | No |
Rane et al 2005 144 | Successful vaginal delivery within 24 hrs | Women with singleton live pregnancies in cephalic presentation undergoing induction of labor at 35 to 42+6 wks for a variety of indications | Prospective cohort | 822 (530; 3) | Logistic | None | None | None | None | Regression formula | No |
Rane et al 2004 143 | Successful vaginal delivery within 24 hrs | Women with singleton live pregnancies in cephalic presentation (occiput posterior position) undergoing induction of labor at 35 to 42+6 wks of gestation for a variety of indications | Prospective cohort | 604 (388; 4) | Logistic | None | None | None | 0.89 | Regression formula | No |
Wing et al 2002 181 | Successful vaginal delivery within 24 hrs | Women with intact membranes and minimal uterine activity, who underwent induction of labor with misoprostol (maximum duration of 24 hrs) | Retrospective cohort | 1373 (657; unclear) | Logistic | None | None | None | None | None | No |
Pandis et al 2001 142 | Successful vaginal delivery within 24 hrs | Singleton pregnancies with live fetus in cephalic presentation undergoing induction of labor with dinoprostone gel at 37-42 wks, mainly for prolonged pregnancy | Prospective cohort | 240 (142; 3) | Cox | None | None | None | None | None | No |
Vaginal delivery within 12 hrs after induction of labor | |||||||||||
Riboni et al 2012 147 | Delivery within 12 hrs | Women who underwent induction of labor at term with dinoprostone gel | Prospective cohort | 115 (42; 6) | Logistic | None | None | None | None | None | No |
Mode of delivery (vaginal or cesarean) after induction of labor | |||||||||||
Gomez-Laencina et al 2012 55 | Cesarean delivery | Women undergoing induction of labor | Prospective cohort | 177 (63; 5) | Logistic | None | None | None | None | Regression formula | No |
Isono et al 2011 71 | Emergency cesarean delivery | Low-risk nulliparous women with premature rupture of membranes who underwent induction of labor | Retrospective cohort | 392 (56; 3) (development sample) | Logistic | Split-sample and crossvalidation | None | Calibration table: fair | 0.73 (internal validation) | Regression formula | No |
Laughon et al 2011 90 | Vaginal delivery | Nulliparous women with vertex singleton undergoing induction of labor at term and delivering between 37-42 wks | Retrospective cohort | 5610 (4224; 4) | Logistic | Bootstrapping | In same paper | None | None | Risk score | No |
Robinson et al 2010 148 | Cesarean delivery | Women undergoing labor induction for preeclampsia with euploid singletons in vertex position | Retrospective cohort | 608 (195; 11) | Logistic, artificial neural network | None | None | P = .50 | 0.74 (logistic); 0.75 (neural network) | None | No |
Rane et al 2005 144 | Cesarean delivery for failure to progress | Singleton live pregnancies in cephalic presentation undergoing induction of labor at 35 to 42+6 wks for variety of indications | Prospective cohort | 822 (91; 5) | Logistic | None | None | None | None | Regression formula | No |
Rane et al 2005 144 | Cesarean delivery (all indications) | Singleton live pregnancies in cephalic presentation undergoing induction of labor at 35 to 42+6 wks for variety of indications | Prospective cohort | 822 (161; 5) | Logistic | None | By Verhoeven et al, 2009 | P = .11 (external validation) | 0.67 (external validation) | Regression formula | No |
Rane et al 2004 143 | Cesarean delivery | Women with singleton live pregnancies in cephalic presentation (occiput posterior position) undergoing induction of labor at 35 to 42+6 wks of gestation for a variety of indications | Prospective cohort | 604 (120; 3) | Logistic | None | None | None | 0.81 | Regression formula | No |
Rane et al 2004 143 | Cesarean delivery | Women with singleton live pregnancies in cephalic presentation (occiput posterior position) undergoing induction of labor at 35 to 42+6 wks of gestation for a variety of indications | Prospective cohort | 604 (120; 3) | Logistic | None | None | None | 0.81 | Regression formula | No |
Herman et al 1993 67 | Cesarean delivery | Pregnant women undergoing induction of labor | Retrospective cohort | 401 (46; 4) | Logistic | None | None | Calibration table shows fair calibration | None | Regression formula, score chart | No |
Mode of delivery | |||||||||||
Benjamin et al 2012 22 | Cesarean delivery for cephalopelvic disproportion | Women with a first term singleton pregnancy | Prospective cohort | 249 (27; 3) | Logistic | None | None | None | None | None | No |
Pitarello et al 2013 130 | Successful vaginal delivery | Women with singleton live term fetus in cephalic presentation | Prospective cohort | 190 (130; 4) | Logistic | None | None | None | 0.80 | Regression formula | No |
Schuit et al 2012 154 | Operative delivery (instrumental vaginal or cesarean for fetal distress or failure to progress | Laboring women with high-risk vertex singleton pregnancies >36 wks of gestation | Randomized trial | 5667 (375 + 212 + 433 + 571; 7) (model A), 5667 (375 + 212 + 433 + 571; 14) (model B), | Multinomial logistic | Bootstrapping | None | Calibration plot shows good calibration | Instrumental vaginal delivery-fetal distress: 0.72 (model A) and 0.73 (modelB2); cesarean-fetal distress: 0.70 (model A) and 0.73 (model B); instrumental vaginal delivery-failure to progress: 0.78 (model A) and 0.80 (model B); cesarean-failure to progress: 0.78 (model A) and 0.81 (model B) | Nomogram in online appendix | No |
Kambale 2011 74 | Cesarean delivery | Pregnant Italian women | Retrospective cohort | 5812 (2102; unclear) | Logistic | None | None | P = .87 | 0.65 | None | No |
Kim et al 2010 81 | Cesarean delivery performed during labor | Nulliparous women with singletons in vertex position, no pregnancy complications, ≥37 wks, intact membranes, no labor, with planned vaginal delivery | Prospective cohort | 453 (57; 3) | Logistic | None | None | P = .47, plot fair | 0.76 | Regression formula | No |
Nader et al 2010 110 | Vaginal delivery | Nulliparous women with singleton pregnancies between 36 and 38 wks of gestation aiming for a vaginal delivery | Prospective cohort | 473 (unclear; 5) | Logistic | None | In same paper | P = .12 (external validation) | 0.70 (external validation) | Regression formula | No |
Rao et al 2008 145 | Cesarean delivery | Singleton pregnancies with a live fetus at 40+4 to 41+6 wks of gestation | Prospective cohort | 1536 (233; 5) | Logistic | None | None | None | 0.75 | Regression formula | No |
Roman et al 2008 149 | Cesarean delivery performed during labor | Women with planned vaginal delivery | Retrospective cohort | 2478 (705; 9) | Logistic | None | None | None | 0.72 | Scoring system | No |
Dietz et al 2006 39 | Normal vaginal delivery (vs operative vaginal or cesarean) | Nulliparous women with an uncomplicated singleton pregnancy and planned for a vaginal delivery | Prospective cohort | 202 (124; 4) | Logistic | None | None | P = .48 | 0.85 | Regression formula | Yes |
Dietz et al 2006 39 | Vaginal delivery (normal or operative, vs cesarean) | Nulliparous women with an uncomplicated singleton pregnancy and planned for a vaginal delivery | Prospective cohort | 202 (149; 5) | Logistic | None | By Nader et al, 2010 | P = .79 P < .0001 on external validation | 0.87 (development); 0.62 (external validation) | Regression formula | Yes |
Akmal et al 2004 11 | Cesarean delivery | Women with singleton pregnancies in cephalic presentation in the early stage of active labor between 37-42 wks of gestation | Cross-sectional cohort | 601 (87; 9) | Logistic | None | None | None | None | Probability table | Yes |
Dulitzki et al 1998 43 | Cesarean delivery | women ≥44 years old who delivered singleton infants; the control group included the women 20-29 years old who delivered singleton infants at immediately after each study subject | Case-control | 418 (56; 3) | Logistic | None | In same paper | None | None | Number of risk factors vs risk | Yes |
Time to delivery | |||||||||||
Pascual-Ramirez et al 2012 124 | Time to vaginal delivery | Women undergoing childbirth who received epidural or combined spinal-epidural analgesia | Randomized trial | 144 (NA; 4) | Cox | None | None | None | None | None | No |
BREECH PRESENTATION | |||||||||||
Successful external cephalic version | |||||||||||
Kok et al 2011 82 | Successful external cephalic version | Women with singletons in breech presentation ≥36 wks | Randomized trial | 310 (122;4) | Logistic | Bootstrapping | By de Hundt et al, 2012 | P = .66, calibration plot shows good fit P = .30 on external validation | 0.71 (development); 0.66 (external validation) | Regression formula | Yes |
Wong et al 2000 182 | Successful external cephalic version | Women with a fetus in breech presentation at ≥36 wks who underwent external cephalic version with the use of tocolytics | Prospective cohort | 53 (34; 4) | None (univariable analysis only) | None | In same paper | Calibration table shows good calibration | None | Risk score | Yes |
Lau et al 1997 89 | Successful external cephalic version | Women that underwent an external cephalic version for breech presentation at ≥36 wks of gestation | Prospective cohort | 243 (169; 3) (total sample) | Logistic | Split-sample | None | None | None | Regression formula, risk groups | No |
Newman et al 1993 112 | Successful external cephalic version | Women that underwent an external cephalic version for breech presentation | Retrospective cohort | 108 (unclear; 5) (development sample) | Linear regression | Split-sample | In same paper | Calibration plot shows reasonable fit | None | Score chart | Yes |
Successful vaginal delivery after external cephalic version | |||||||||||
Chan et al 2004 33 | Successful vaginal delivery after external cephalic version | Women with singleton pregnancies who had a single attempt of external cephalic version ≥36 wks of gestation | Prospective cohort | 192 (unclear; 5) (development sample) | Logistic | Split-sample | None | None | 0.71 | Regression formula | No (authors acknowledge model not effective enough for routine use) |
Mode of delivery | |||||||||||
Broche et al 2008 29 | Mode of delivery (vaginal birth or cesarean delivery) | Women with singletons in breech presentation >37 wks indexed for vaginal birth trial | Retrospective cohort | 376 (80; 5) | Logistic | None | None | None | None | None | No |
INFECTION AND INFLAMMATION | |||||||||||
Intraamniotic infection and/or inflammation | |||||||||||
Park et al 2012 123 | Intraamniotic infection and/or inflammation | Pregnant women with PPROM | Partly prospective, partly retrospective cohort | 171 (63; 4) | Logistic | None | None | P = .52 | 0.85 | Regression formula | No |
Jung et al 2011 73 | Intraamniotic inflammation | Women admitted with preterm labor and intact membranes between 21 and 35 wks of gestation, with a singleton live fetus without major congenital anomalies, ≤3 cm cervical dilatation | Cross-sectional cohort | 153 (30; 3) | Logistic | None | None | P = .75 | 0.724 | Regression formula | No |
Clinical infection | |||||||||||
Kayem et al 2009 76 | Clinical infection | Women hospitalized for preterm labor | Prospective cohort | 371 (21; 5) | Logistic | Crossvalidation | None | None | 0.82 (development) | Risk score | No |
Histologic signs of infection | |||||||||||
Cobo et al 2012 34 | Histological funisitis | Pregnant women with diagnosed PPROM | Prospective cohort | 107 (19; 3) | Logistic | None | None | None | 0.89 | None | No |
FETAL HEALTH AND SURVIVAL | |||||||||||
Miscarriage or early fetal loss | |||||||||||
van Ravenswaaij et al 2011 174 | Miscarriage <16 wks | Women who underwent first trimester screening | Retrospective cohort | 28566 (150; 3) | Logistic | None | None | None | 0.78 | Regression formula | No |
Dugoff et al 2008 42 | Early fetal loss | Women with singleton pregnancies | Randomized trial | 35253 (318; 7) | Unclear | None | None | None | None | None | No |
Stillbirth | |||||||||||
Reddy et al 2010 146 | Antepartum stillbirth | Singleton deliveries ≥23 wks of gestation | Retrospective cohort | 174809 (712; unclear) | Cox | None | None | None | None | None | No |
Smith et al 2007 160 | Stillbirth ≤33 wks | Pregnant women at 22-24 wks of gestation | Retrospective cohort | 30519 (unclear; 4) | Logistic | None | None | None | 0.87 | Regression formula | No |
Smith et al 2007 160 | Stillbirth ≥34 wks | Pregnant women at 22-24 wks of gestation | Retrospective cohort | 30519 (unclear; 3) | Logistic | None | None | None | 0.67 | Regression formula | No |
Perinatal mortality or survival | |||||||||||
de Caunes et al 1990 35 | Perinatal mortality (fetal death with birthweight >500 g or death within 7 days of live birth) | Singleton deliveries | Case-control | 746 (208; 10) (total sample) | Unclear | Split-sample | None | Calibration plot: no clear interpretation | None | Score chart | No |
Block and Rahhal 1976 26 | Perinatal survival | Women undergoing cerclage beyond 12 wks | Retrospective cohort | 31 (unclear; 5) | None | None | None | None | None | Score chart | No |
Poor perinatal outcome | |||||||||||
Romero et al 2001 150 | Fetal wellbeing (1 minute Apgar score <6 or admission to NICU) | Hypertensive pregnancies at 36-42 wks | Prospective cohort | 171 (8; 5) | Logistic | None | None | None | None | Regression formula | No |
Weenink et al 1984 177 | Unfavorable fetal outcome (perinatal death or prolonged NICU stay) | Women with pregnancy-induced or aggravated hypertension | Prospective cohort | 57 (27; 3) | Logistic | None | None | None | None | None | No |
COMPLICATIONS OF PREGNANCY AND DELIVERY | |||||||||||
Hypertensive disorders (combined) or placenta-related complications | |||||||||||
Abdelaziz et al 2012 10 | Hypertensive disorders (preeclampsia and PIH) | Women with singleton pregnancies without a priori high risk of pregnancy-induced hypertensive complications | Nested case-control | 267 (89; 3) | Logistic | None | None | None | 0.79 | None | No |
van Ravenswaaij et al 2011 174 | Placenta-related complications (low birthweight, stillbirth, PIH, preeclampsia, HELLP) | Women who underwent first trimester screening | Retrospective cohort | 28566 (1074; 4) | Logistic | None | None | None | 0.56 | Regression formula | No |
Mello et al 2001 106 | Pregnancy induced hypertensive disorders (PE and IUGR) | Normotensive white women with singleton pregnancies at high risk for preeclampsia and IUGR (insulin-dependent diabetes mellitus, previous preeclampsia, recurrent abortions or previous stillbirth) | Prospective cohort | 187 (47; 9) (models A and B) (development sample) | Artificial neural network | Split sample | None | None | 0.95 (model A) and 0.85 (model B) | None | No |
Placenta previa | |||||||||||
Odibo et al 2007 116 | Placenta previa | Women with a previous cesarean delivery | Retrospective cohort | 25076 (361; 7) | Logistic | None | None | None | 0.59 | None | No |
Shoulder dystocia | |||||||||||
Dodd et al 2012 40 | Shoulder dystocia | Pregnant women | Retrospective cohort | 114827 (1303; 4) | Logistic | None | None | P = .04 | 0.73 | None | No |
Gupta et al 2010 63 | Shoulder dystocia | Women without pre-existing or gestational diabetes or previous shoulder dystocia with singleton vaginal live cephalic deliveries at ≥36 wks | Retrospective cohort | 20142 (120; 3) (model A) and 20142 (120; 7) (model B) (development sample) | Logistic | Split-sample | None | results not reported but “no strong evidence of poor fit” | 0.90 (model A) and 0.69 (model B) | Regression formula | No |
Gross et al 1987 61 | Shoulder dystocia (with and without trauma) | Women delivering neonates with birthweights ≥4000 g | Unclear | 394 (29+20; 3) | Three-way discriminant analysis | None | None | None | None | None | No |
Birth trauma | |||||||||||
Levine et al 1984 93 | Birth trauma: brachial plexus injury | Women with a singleton term live birth | Retrospective cohort | 13870 (36; 5) | Logistic | None | None | None | None | Score chart | No |
Levine et al 1984 93 | Birth trauma: clavicular fracture | Women with a singleton term live birth | Retrospective cohort | 13870 (28; 6) | Logistic | None | None | None | None | Score chart | No |
Levine et al 1984 93 | Birth trauma: facial nerve injury | Women with a singleton term live birth | Retrospective cohort | 13870 (104; 6) | Logistic | None | None | None | None | Score chart | No |
Placental abruption | |||||||||||
Odibo et al 2007 116 | Placental abruption | Women with a previous cesarean delivery | Retrospective cohort | 25076 (309; 7) | Logistic | None | None | “good fit” but statistics not reported | 0.61 | None | No |
Lindqvist and Happach 2006 95 | Placental abruption | Unselected pregnant women | Case-control | 2483 (112; 10) | None (only univariable analysis) | None | None | None | None | Risk score | No |
Baumann et al 2000 21 | Placental abruption | Primiparous women with singleton pregnancies | Retrospective cohort | 80336 (382; 10) | Logistic | None | None | None | None | Regression formula | No |
Baumann et al 2000 21 | Placental abruption | Multiparous women with singleton pregnancies | Retrospective cohort | 89889 (492; 12) | Logistic | None | None | None | None | Regression formula | No |
Postpartum hemorrhage | |||||||||||
Biguzzi et al 2012 25 | Postpartum hemorrhage | Women with a singleton vaginal delivery ≥37 wks | Unclear | 6011 (1435; 6) | Logistic | Bootstrapping | None | Based on calibration plot: good fit | 0.70 | Nomogram | No |
Prata et al 2011 140 | Postpartum hemorrhage | Women expecting a singleton vaginal delivery | Prospective cohort | 2510 (93; 20) | Logistic | None | None | None | None | Number of risk factors vs risk | No |
Tsu 1994 170 | Postpartum hemorrhage | Women with singleton pregnancies and spontaneous onset of labor | Case-control | 653 (151; 5) | Logistic | None | None | None | Only ROC curve, AUC not reported | None | No |
Anal sphincter injury | |||||||||||
Williams et al 2005 180 | Anal sphincter injury | Women with term singleton deliveries | Case-control | 246 (123; unclear) | Logistic | None | None | None | Not shown but “ROC curve approximated to a straight line demonstrating very poor discrimination” | Risk score | No |
Thrombosis | |||||||||||
Lindqvist et al 2002 94 | Thrombosis in pregnancy (deep venous thrombosis, pulmonary embolism, or cerebral thromboembolism) | Unselected pregnancies | Prospective cohort | 2384 (3; 8) | Logistic | None | None | None | None | Internet-based risk calculator (not available anymore) | Yes |
Lindqvist et al 2002 94 | Thrombosis within 3 mos’ postpartum (deep venous thrombosis, pulmonary embolism, or cerebral thromboembolism) | Unselected pregnancies | Prospective cohort | 2384 (3; 10) | Logistic | None | None | None | None | Internet-based risk calculator (not available anymore) | Yes |
Maternal complications of attempted VBAC | |||||||||||
Scifres et al 2011 155 | Major maternal morbidity after attempted VBAC (any of the following): uterine rupture, bladder or ureteral injury, bowel injury, or uterine artery laceration | Women with prior cesarean deliveries who attempted VBAC | Retrospective cohort | 13706 (300; 6) | Logistic | None | None | None | 0.65 | None | No (performance too poor for use in practice) |
Macones et al 2006 99 | Uterine rupture after attempted VBAC | Women with prior cesarean deliveries who attempted VBAC | Nested case-control | 799 (134; 4) (model A) and 799 (134; 6) (model B) | Logistic | None | None | None | 0.68 (model A) and 0.71 (model B) | None | No |
Maternal complications of preeclampsia | |||||||||||
von Dadelszen et al 2011 176 | Maternal mortality or one or more serious CNS, cardiorespiratory, hepatic, renal, or haematological morbidity in women with preeclampsia | women who were admitted with preeclampsia or had developed preeclampsia after admission | Prospective cohort | 1935 (106; 6) | Logistic | Bootstrapping | None | Good calibration (based on table) | 0.88 | Regression formula | No |
van der Tuuk et al 2011 171 | Progression to a high risk situation (any of the following: diastolic blood pressure ≥110 mmHg, systolic blood pressure ≥170 mmHg and⁄or proteinuria ≥5 g in 24 h, eclampsia, HELLP syndrome or maternal mortality) | women with asingleton in cephalic presentation between 36-41 wks and gestational hypertension or mild preeclampsia managed expectantly | Randomized trial | 730 (244; 12) | Logistic | Bootstrapping | None | P = .40 | 0.71 | None | No |
Combined adverse pregnancy outcome | |||||||||||
Magann et al 2011 100 | At least one of the following adverse outcomes: preeclampsia, gestational diabetes, induction of labor, cesarean delivery, postpartum hemorrhage, postterm delivery, endometritis, wound infection, neonate born large for gestational age, perinatal death, and neural tube defects | Women with singleton pregnancies | Retrospective cohort | 4500 (2308; 4) | Recursive partitioning followed by logistic | None | None | None | None | Risk for specified risk groups | No |
OTHER | |||||||||||
Short cervix | |||||||||||
Souka et al 2011 162 | Short cervix (≤15 mm) at 20-24 wks of gestation | Women with viable singleton pregnancies presenting at 11-14 wks | Prospective study | 800 (12; 3) (model A); 800 (12; 4) (model B) | Logistic | None | None | P = .22 (model A); P > .05 (model B) | 0.81 (model A); 0.88 (model B) | Probability curve | No |
Higher corticotrophin-releasing hormone levels | |||||||||||
Latendresse and Ruiz 2010 88 | Higher corticotrophin-releasing hormone levels (≥15 pcg/mL) at 14-20 wks | Women with “healthy” singleton pregnancies | Cross-sectional cohort | 84 (16; 3) | Logistic | None | None | P = .071 | None | Regression formula | No |