Theory of obstetrics: An epidemiologic framework for justifying medically indicated early delivery
© Joseph; licensee BioMed Central Ltd. 2007
Received: 05 August 2005
Accepted: 28 March 2007
Published: 28 March 2007
Modern obstetrics is faced with a serious paradox. Obstetric practice is becoming increasingly interventionist based on empirical evidence but without a theoretical basis for such intervention. Whereas obstetric models of perinatal death show that mortality declines exponentially with increasing gestational duration, temporal increases in medically indicated labour induction and cesarean delivery have resulted in rising rates of preterm birth and declining rates of postterm birth. Other problems include a disconnection between patterns of gestational age-specific growth restriction (constant across gestation) and gestational age-specific perinatal mortality (exponential decline with increasing duration) and the paradox of intersecting perinatal mortality curves (low birth weight infants of smokers have lower neonatal mortality rates than the low birth weight infants of non-smokers).
The fetuses at risk approach is a causal model that brings coherence to the various perinatal phenomena. Under this formulation, pregnancy complications (such as preeclampsia), labour induction/cesarean delivery, birth, revealed small-for-gestational age and death show coherent patterns of incidence. The fetuses at risk formulation also provides a theoretical justification for medically indicated early delivery, the cornerstone of modern obstetrics. It permits a conceptualization of the number needed to treat (e.g., as low as 2 for emergency cesarean delivery in preventing perinatal death given placental abruption and fetal bradycardia) and a calculation of the marginal number needed to treat (i.e., the number of additional medically indicated labour inductions/cesarean deliveries required to prevent one perinatal death). Data from the United States showed that between 1995–96 and 1999–2000 rates of labour induction/cesarean delivery increased by 45.1 per 1,000 and perinatal mortality decreased by 0.31 per 1,000 total births among singleton pregnancies at > = 28 weeks of gestation. The marginal number needed to treat was 145 (45.1/0.31), showing that 145 excess labour inductions/cesarean deliveries in 1999–2000 (relative to 1995–96) were responsible for preventing 1 perinatal death among singleton pregnancies at > = 28 weeks gestation.
The fetuses at risk approach, with its focus on incidence measures, provides a coherent view of perinatal phenomena. It also provides a theoretical justification for medically indicated early delivery and reconciles the contemporary divide between obstetric theory and obstetric practice.
Increases in medically indicated labor induction and cesarean delivery in recent decades have resulted in increases in preterm (< 37 weeks) birth rates, while births at term (37–41 weeks) and postterm (≥ 42 weeks) gestation are also being delivered much earlier than previously [1–10]. However, such changes in obstetric practice are not consistent with obstetric theory since traditional obstetric models of perinatal death show that perinatal mortality rates decrease exponentially as gestational age increases [11–14]. This paper examines the 'paradox of modern obstetrics'  and various other conundrums within perinatology and discusses the 'fetuses at risk approach' as a potential solution. The latter approach is an epidemiologic formulation that identifies fetuses as the candidates for perinatal events (as opposed to the traditional obstetric and epidemiologic models that typically focus on newborns as the candidates for perinatal events). The fetuses at risk approach provides a coherent framework for reconciling the diverse set of problems facing perinatology [15, 16] and for developing a coherent epidemiologic framework for justifying medically indicated early delivery.
1.1. The paradox of modern obstetrics
The cornerstone of modern obstetrics is selective, carefully timed early delivery given fetal compromise (maternal indications sometimes necessitate early delivery as well). Medically indicated labor induction and cesarean delivery are typically employed when the balance of risks and benefits indicate that birth and supportive neonatal care are preferable to an intrauterine environment that is adversely affecting fetal well-being.
However, traditional epidemiologic and obstetric models of perinatal death do not support this iatrogenic increase in early delivery [11–14]. Such models show that the rate of gestational age-specific perinatal mortality (calculated by dividing the number of perinatal deaths at any gestation by the number of total births at that gestation) decreases exponentially as gestational age advances (Figure 1b). Although such models provide a justification for early delivery at ≥ 41 weeks for singletons and at ≥ 39 weeks for twins (Figure 1b), they suggests that a left-shift in the gestational distribution in the preterm or term gestational age range will lead to increases in overall perinatal mortality rates. For instance, early delivery at 34 weeks instead of 36 weeks gestation (or early delivery of singletons at 38 instead of 40 weeks) implies a substantially higher perinatal mortality rate (note log scale, Figure 1b). In fact, the recent left-shift in the gestational age distribution in Canada and in the United States (due to increases in labor induction and cesarean delivery) was accompanied by a decline in perinatal mortality [1, 4, 7–9, 21–23].
1.2. Other apparently contradictory phenomena in the perinatology
The paradox of modern obstetrics is also evident in relation to cerebral palsy. Although preterm birth is highly associated with cerebral palsy and deemed to be an important cause of cerebral palsy [11, 24], the rising rate of preterm birth (especially among twins) has not resulted in an epidemic of cerebral palsy. Related conundrums are evident in the literature on fetal growth restriction [15, 16]. The methods used to identify small-for-gestational age (SGA) live births (< 3rd or < 10th percentile of birth weight for gestational age) suggest that a fixed fraction of births (approximately 3% or 10% depending on the cut-off used) are growth restricted at each gestation. Such an implied constancy of the growth restriction rate across gestation is at odds with an exponentially declining rate of gestational age-specific perinatal mortality. Clearly, this incongruence between patterns of in utero growth faltering and death needs to be reconciled, given the known relationship between fetal growth restriction and perinatal death [25, 26].
Other problems in the fetal growth literature relate to fetal growth standards. Some fetal growth standards provide unisex reference values [27–30], several are sex-specific [25, 31–40] and yet others provide both sex-specific and unisex reference values [41–44]. Of equal concern is the fact that several fetal growth standards are customized for different races [25, 31, 33–36], parity [31, 33, 35, 40, 42], plurality [30, 36] and other characteristics [30, 33], while others are not [27–29, 32, 37–39, 41, 43].
Perhaps the most intriguing of the paradoxes in the perinatal literature is presented by intersecting birth weight- and gestational age-specific perinatal mortality curves. Birth weight-and gestational age-specific perinatal mortality curves intersect  when contrasts are made by smoking status, plurality (Figure 1b), race, parity, infant sex, country, etc. This phenomenon was first identified by Yerushalmy  who showed that whereas, at low birth weight, infants of smokers have a lower neonatal mortality rate than infants of non-smokers, the reverse is true at higher birth weight. Are the low birth weight or preterm infants of smokers more healthy than the low birth weight or preterm infants of nonsmokers? Addressing the paradox of intersecting perinatal mortality curves is important because the resolution of scientific paradoxes often leads to greater substantive insights. The contemporary appeal of traditional models notwithstanding, intersecting perinatal mortality curves (and the other above-mentioned conundrums) suggest that there may be a more compelling perspective on perinatal events.
2.1 Problems with traditional models
The conundrums and paradoxes evident in contemporary perinatology are, at least partly, a consequence of the manner in which time related concepts are addressed in traditional models.
2.1.1. Time scales and anchors
Two time scales are commonly used in perinatology and these measure the duration of life in utero (gestational age, which is anchored to the first day of the last menstrual period) and the duration of life after birth (chronologic age, which is anchored to birth). The clinical problems caused by these dual overlapping scales are generally recognized, especially by clinicians in neonatology, who resort to a single scale for expressing age, namely, post-menstrual age or corrected gestational age. Such recognition is also reflected in the evolution of Bronchopulmonary Dysplasia, which was historically defined as a requirement for oxygen at more than 28 days after birth but now refers to a requirement for oxygen or ventilatory support at 36 weeks of post-menstrual age . An important aspect of the use of dual time scales that is not related to duration issues is the qualitative label that is assigned to death depending on whether death occurs before or after the second time scale becomes operational. Thus, a fetus who dies in utero at 38 weeks is a stillbirth but another who dies at 2 weeks of chronologic age after birth at 36 weeks is a neonatal death. Birth has a preeminent position in qualifying life events for reasons that appear to be more sociologic than biologic.
2.1.2. Status of gestational age: determinant versus survival time
Gestational age is often treated as a determinant in perinatal epidemiologic studies. As a determinant, gestational age at birth (and birth weight, which is closely correlated with gestational age) serves as a powerful predictor of death and other adverse perinatal outcomes. However, from an epidemiologic perspective, gestational age is in fact follow up (survival) time and should be treated as such in causal models.
2.2. The fetuses at risk approach
2.2.1. Incidence of birth, labour induction, pregnancy complications
Numbers and rates of perinatal death, live birth and small for gestational age (SGA) live birth among singletons births, Canada (excluding Ontario), 1991 to 1997.
SGA live births
Fetuses at risk†
Rates (Fetuses at risk)
Perinatal mortality per 1,000
Births per 1,000
R-SGA per 1,000
Perinatal mortality per 1,000
Numbers and rates of perinatal death, live birth and small for gestational age (SGA) live birth among twin births, Canada (excluding Ontario), 1991 to 1997.
SGA live births
Fetuses at risk†
Rates (Fetuses at risk)
Perinatal mortality per 1,000
Births per 1,000
R-SGA per 1,000
Perinatal mortality per 1,000
2.2.2. The incidence of growth restriction
The incidence of growth restriction is a good example of an index whose estimation presents a challenge. Although routine obstetric practice includes screening for and diagnosis of growth restriction, the technology is insufficiently advanced to permit valid and complete ascertainment of all new cases at each gestation [63–65]. Given this limitation, an alternative index, namely, the incidence of revealed SGA (Tables 1, 2, Figure 1c, Figure 3) may be calculated by dividing the number of SGA births at any gestation by the number of fetuses at risk of SGA birth at that gestation [15, 16, 57–59]. The primary utility in estimating this proxy incidence rate is in order to approximate the incidence pattern of growth restriction with increasing gestational duration i.e., to estimate whether it increases, decreases or remains constant. The measure cannot provide the absolute rate of SGA at any gestation since the numerator of the index is dependant on birth (hence the term "revealed"). Improvements in technology will permit quantification of the absolute rate (incidence) of growth restriction at each gestation in the future.
2.2.3. The incidence of perinatal death
As mentioned, the extended fetuses at risk model most deviates from traditional models with respect to events that occur after birth and yet have a prenatal etiology. Under the traditional model of perinatal death, neonatal deaths occur among infants in the first month after birth and the unborn fetus is not a candidate for neonatal death. However from a broad biological, obstetric and ultimately epidemiologic point of view, a fetus at any gestation is at risk of stillbirth and neonatal death at that gestation. If one considers a woman at 28 weeks gestation with severe preeclampsia and fetal compromise, the risk of stillbirth is easy to conceptualize. The risk of neonatal death is substantial as well and can follow either premature labour or medically indicated delivery. The same risks apply in concept to a woman with a healthy pregnancy at 28 weeks gestation, despite the magnitude of the risks being considerably smaller . Thus, although neonatal deaths literally occur among infants, fetuses can be considered candidates for neonatal death as well. This is analogous to the calculation of age-specific rates of death from breast cancer. Such rates are calculated using all women in the population as the denominator (i.e., as candidates for death from breast cancer), although one could argue that death from breast cancer can only occur among women with breast cancer.
The extended fetuses at risk formulation of death provides 2 alternative models that treat time per epidemiologic principles (as survival time and on a single time scale). In the first model, namely, the comprehensive model of death, time is measured on the scale of post-menstrual (or post conceptional) age with fetuses/infants censored at death . Birth is ignored as a event (for truncating the original time scale) and no distinction is made between deaths that occur before and after birth. The epidemiologic risk set at any point in post-menstrual time is constituted by the fetuses/infants at risk of death at that point in time . When this framework is integrated into a proportional hazards model, birth may be introduced as a time-dependant covariate with time-varying effects . In the second model, namely, the obstetric model of death, time is measured on the scale of gestational age with fetuses censored at birth or death. All deaths that have their origins in prenatal or labour and delivery events are deemed relevant to obstetrics. Thus, as per traditions in obstetrics, stillbirths and neonatal deaths (and serious neonatal morbidity) are assigned to the point of birth. The epidemiologic risk set for such obstetric outcomes is constituted by the fetuses at risk for such events, namely, all unborn fetuses at the gestational age in question (Figure 4).
2.2.4. Reconciling diverse perinatal conundrums
The fetuses at risk formulation brings coherence to the study of perinatal phenomena. It shows that the incidence of pregnancy complications such as preeclampsia and chorioamnionitis increases as gestational age advances [61, 62]. Revealed SGA rates also increase with increasing gestational age (Figure 1c) and presage the rise in perinatal mortality rates [15, 16, 57–59]. Gestational age-specific perinatal mortality curves do not intersect in comparisons by smoking status, plurality (Figure 1c), race, parity, infant sex, etc [57–59]. Smokers have higher rates of revealed SGA and perinatal death than non-smokers at all gestational ages  and twins  have higher rates of revealed SGA and perinatal death than singletons at all gestational ages (Figure 1c). Similarly, the incidence of birth, labor induction and cesarean delivery show patterns that are congruent with patterns of revealed SGA and death [15, 57–59, 67]. The rising patterns of gestational age-specific revealed SGA and perinatal death also offer a preliminary justification for medically-indicated early delivery. Finally, the fetuses at risk approach provides insights into issues as diverse as the etiology of cerebral palsy  and the need for customized fetal growth standards [59, 75]. Specifically, it shows that the rate of critical neurologic injury that causes cerebral palsy increases with advancing gestational age  and suggests that the pregnancy complications (which precede preterm birth) are the cause of cerebral palsy (and not preterm birth itself). With regards to fetal growth standards, the fetuses at risk formulation shows that perinatal mortality patterns are consistent with separate fetal growth standards for males and females but not with the available separate standards for blacks and whites in the United States .
The fetuses at risk formulation faces its most serious challenge from the traditional idea that perinatal mortality declines as gestational age increases. Indeed, this latter inference appears intuitive and is corroborated by the readily apparent relationship between birth weight and perinatal mortality. Despite the socially important prognostic purpose served by the traditional model of perinatal death, it is not appropriate as a causal model. The use of dual overlapping time scales for life in utero (gestational age) and after birth (chronologic age) and the truncation of the full biologic continuum (as in the calculation of neonatal mortality rates using live births at a particular gestational age as the denominator) is problematic on the level of first principles and also because it is responsible for numerous paradoxes and conundrums . The entire mortality experience of a cohort of fetuses (as documented on single time scale) is of interest, irrespective of whether death precedes or follows birth (see Figure 4).
As for explaining the rise in growth restriction and perinatal mortality rates with increasing gestation, one can speculate that the ability of the utero-placental system to support the fetus declines with increasing gestational age. Rising rates of growth restriction (as reflected in rising rates of revealed SGA) and perinatal death with increasing gestational duration reflect increases in the incidence of pregnancy complications such as preeclampsia and chorioamnionitis [61, 62] and also other stochastic processes that adversely affect vascular function within the utero-placental system.
The above-mentioned arguments suggest that the traditional and fetuses at risk models serve vastly different purposes. The distinction between descriptive versus causal models is particularly relevant in this context ; traditional models which truncate the biologic continuum are better viewed as descriptive (noncausal) models which are ideal for setting prognosis at birth, while the fetuses at risk formulation represents a causal model that yields biologic insights and provides the basis for obstetric intervention .
2.3. An epidemiologic framework for medically indicated early delivery
Developing an explicit epidemiologic framework for justifying medically indicated early delivery is important in order to avoid conflicts between obstetric theory and practice . Thus, in the absence of appropriate obstetric theory, population increases in preterm birth (occurring secondary to increases in medically indicated preterm birth) may be viewed as adverse developments under the traditional theoretical framework. This would lead to a discounting of the perinatal mortality reductions that are a consequence of recent changes in the management of compromised fetuses at preterm gestation [1, 4, 7–9, 21–23]. Also, the obstetric literature needs to be more articulate with respect to the number of labor inductions and cesarean deliveries that are needed to prevent one perinatal death or serious neonatal morbidity (given a particular domain/indication). The proposed epidemiologic framework based on the fetuses at risk model is illustrated below using live births and stillbirths in the United States between 1995–1996 and 1999–2000 (National Center for Health Statistics perinatal mortality data file for all states and the District of Columbia). Perinatal mortality was defined to include stillbirths and neonatal deaths  but excluded perinatal deaths due to congenital anomalies (in order to eliminate the potential effect of temporal increases in prenatal diagnosis and pregnancy termination for major congenital anomalies ).
2.3.1. Incidence of medically indicated early delivery, birth, revealed SGA, and death
2.3.2. Number needed to treat
The number needed to treat (NNT), an index widely used in therapeutics as part of risk-benefit equations, is insufficiently articulated in connection with medically indicated early delivery . This is in part because conventional models of perinatal mortality imply that early delivery is associated with an increased rate of perinatal death (Figure 1b). Nevertheless, the concept of the NNT remains as relevant and critical in the context of medically indicated early delivery as elsewhere in medicine. The NNT for medically indicated early delivery (given a specific indication) may be defined as the reciprocal of the difference between the rate of perinatal mortality or serious neonatal morbidity given no obstetric intervention and the rate of perinatal mortality or serious neonatal morbidity given medically indicated early delivery.
2.3.3. Number needed to treat under different scenarios
The clinical scenarios described below are characterized by varying background rates of perinatal mortality (which substantially modify the NNT). The first scenario involves an obstetric emergency (e.g., placental abruption with fetal bradycardia) where a rapid absolute increase in the (incidence density) rate of perinatal death is anticipated over a short time span (minutes). It is expected that an emergency cesarean delivery carried out within 15–30 minutes will prevent perinatal death in more than half the fetuses . This implies an NNT of approximately 2 or less. Similarly, in a second scenario involving a serious pregnancy complication and fetal compromise (e.g., severe preeclampsia with fetal growth restriction), an expected perinatal mortality reduction due to labor induction and/or cesarean delivery (as opposed to no intervention) of about 100 to 200 per 1,000 fetuses implies an NNT of 5 to 10. A third scenario involves routine delivery of twin pregnancy at 38 weeks gestation. If routine delivery at 38 weeks (relative to no obstetric intervention) reduces the rate of perinatal mortality by about 5 per 1,000 fetuses, this implies an NNT of 200. The final scenario involves routine delivery at 41 weeks gestation given an uncomplicated singleton pregnancy. If the difference between perinatal mortality given routine delivery at 41 weeks versus spontaneous delivery without obstetric intervention is approximately 1 per 1,000 fetuses at risk, this implies an NNT of 1,000. In other words, 1,000 routine early deliveries at 41 weeks gestation (through labor induction and/or cesarean delivery) would prevent one perinatal death.
2.3.4. Problems with the NNT calculation
Virtually all estimates used in the NNT calculations above are speculative even if they represent more or less reasonable approximations. In fact, most inputs into the NNT calculation cannot be estimated given current standards of care since the decision not to intervene is such situations (e.g., severe preeclampsia with fetal compromise) would constitute a breach of ethical standards.
2.3.5. Marginal NNT calculation
The marginal NNT, which measures the effect of increases in medically indicated early delivery (beyond standard rates of medically indicated early delivery), is an alternative measure that is directly pertinent to obstetric practice. In this calculation, a temporal increase in medically indicated early delivery is set against the change in perinatal mortality in any particular domain.
Rates of labor induction and/or cesarean delivery, perinatal mortality (excluding congenital malformations) and the marginal number needed to treat in order to prevent one perinatal death in various subpopulations, United States, 1995–96 and 1999–2000.
Labor induction/cesarean deliveries per 1,000 fetuses
Perinatal deaths*/1,000 fetuses
Number needed to treat (marginal)
Singletons ≥ 28 weeks, all
≥ 28 weeks, no medical risk factors
≥ 28 weeks, with hypertension
≥ 28 weeks, with diabetes
≥ 28 weeks, with hyp. and diabetes
Twins ≥ 28 weeks, all
Singletons ≥ 34 weeks, all
≥ 34 weeks, no medical risk factors
≥ 34 weeks, with hypertension
≥ 34 weeks, with diabetes
≥ 34 weeks, with hyp. and diabetes
Twins ≥ 34 weeks, all
Such marginal NNT calculations are analogous to calculations based on randomized trials which contrast routine induction of labor vs selective induction of labor at or beyond term  or those which contrast aggressive vs expectant management given severe preeclampsia before term gestation . A meta-analysis  of studies on the former issue showed that routine induction of labor reduced perinatal death rates several-fold (odds ratio of 0.20, 95% confidence interval 0.06 to 0.70). This implies an NNT of 1,250 for routine induction of labour at or beyond term gestation, assuming a perinatal mortality rate of 1.0 per 1,000 fetuses at risk following selective labor induction.
The proposed framework is based on two important assumptions. First, medically indicated early delivery is considered the final pathway for obstetric intervention. Thus, increases in labor induction and cesarean delivery are credited with preventing perinatal death even though such early delivery was facilitated by improved methods for assessing fetal well-being and supportive neonatal care. Early delivery is thus viewed as a therapeutic package which subsumes antenatal monitoring, diagnosis of fetal well-being, supportive neonatal care and other interventions that permit higher rates of early delivery to rescue compromised fetuses from a hostile intrauterine environment.
A second assumption is that temporal increases in labor induction and cesarean delivery rates and declines in perinatal mortality rates reflect true changes in obstetric practice (rather than changes in population characteristics). It is possible that changes in maternal characteristics (such as increases in older maternal age and pre-pregnancy obesity [83, 84]) may have been partly responsible for changes in labor induction, cesarean delivery and perinatal mortality rates in the United States between 1995–96 and 1999–2000. Although such changes are unlikely to have affected the results substantially (since the study interval was only 4 years), regression adjustment can be used to address this issue where necessary.
Current limitations of the fetuses at risk approach include an inability to precisely document the incidence of fetal growth restriction. This is because diagnosis of growth faltering in utero, although much facilitated in recent decades through ultrasonographic means, remains inaccurate and essentially unavailable at the population level [63–65]. The alternative index of revealed SGA  is useful but limited by its relationship to birth rate patterns. Further developments in ultrasound technology are needed so that incidence rates can be estimated more accurately based on an identification of all new cases of growth restriction (in utero). Another approximation in the fetuses at risk approach relates to the timing of the pathologic process or event. Assigning events such as neonatal death and serious neonatal morbidity to the moment of birth often involves a systematic overestimation of the timing of the critical pathologic process or event . The systematic nature of the problem means that the incidence patterns of perinatal mortality and morbidity are not seriously affected, however.
The cornerstone of modern obstetrics, namely, early delivery given fetal compromise, cannot be reconciled with traditional models of perinatal mortality which show that perinatal death rates decline exponentially as gestational duration increases. On the other hand, the fetuses at risk approach, which shows that pregnancy complications, revealed SGA and perinatal death rates increase with increasing gestational age, provides a justification for medically indicated early delivery and also resolves several prevailing conundrums in the perinatal field. Although inputs for estimating therapeutic indices related to medically indicated early delivery (such as the NNT) cannot be obtained for ethical reasons, it is possible to retrospectively estimate the marginal NNT associated with medically indicated early delivery. This provides an estimate of the number of additional medically indicated early deliveries that were required to prevent one perinatal death. On a more general level, the traditional model of perinatal death and the fetuses at risk approach are best viewed as serving different purposes; the former is suited for setting prognosis at birth while the latter provides a causal framework and the basis for obstetric intervention.
Access to the Canadian data (from the Vital Statistics Registrars of the provinces and territories) and to data from the United States (from the National Centre for Health Statistics) is gratefully acknowledged. The author is indebted to the Canadian Perinatal Surveillance System- much of this paper is based on previously published work carried out with colleagues in the Canadian Perinatal Surveillance System. Dr. Joseph is supported by a Peter Lougheed New Investigator award from the Canadian Institutes of Health Research.
- Health Canada: Canadian Perinatal Health Report 2003. Ottawa: Minister of Public Works and Government Services Canada. 2003Google Scholar
- Health Canada: Canadian Perinatal Health Report 2000. Ottawa: Minister of Public Works and Government Services Canada. 2000Google Scholar
- Millar WJ, Wadhera S, Nimrod C: Multiple births: trends and patterns in Canada, 1974–1990. Health Rep. 1992, 4: 223-50.PubMedGoogle Scholar
- Joseph KS, Kramer MS, Marcoux S, Ohlsson A, Wen SW, Allen A, Platt R: Determinants of preterm birth rates in Canada from 1981 through 1983 and from 1992 through 1994. New Engl J Med. 1998, 339: 1434-9. 10.1056/NEJM199811123392004.View ArticlePubMedGoogle Scholar
- Breart G, Blondel B, Tuppin P, Grandjean H, Kaminski M: Did preterm deliveries continue to decrease in France in the 1980s?. Paediatr Perinat Epidemiol. 1995, 9: 296-306.View ArticlePubMedGoogle Scholar
- Foix-L'Helias L, Blondel B: Changes in risk factors of preterm delivery in France between 1981 and 1995. Paediatr Perinat Epidemiol. 2000, 14: 314-23. 10.1046/j.1365-3016.2000.00300.x.View ArticlePubMedGoogle Scholar
- Joseph KS, Demissie K, Kramer MS: Obstetric intervention, stillbirth, and preterm birth. Semin Perinatol. 2002, 26: 250-9. 10.1053/sper.2002.34769.View ArticlePubMedGoogle Scholar
- Ananth CV, Joseph KS, Oyelese Y, Demissie K, Vintzileos AM: Trends in preterm birth and perinatal mortality among singletons: United States, 1989 through 2000. Obstet Gynecol. 2005, 105: 1084-91.View ArticlePubMedGoogle Scholar
- Ananth CV, Joseph KS, Demissie K, Vintzileos AM: Trends in twin preterm birth subtypes in the United States, 1989 through 2000: impact on perinatal mortality. Am J Obstet Gynecol. 2005, 193: 1076-82.View ArticlePubMedGoogle Scholar
- Sue-A-Quan AK, Hannah ME, Cohen MM, Foster GA, Liston RM: Effect of labour induction on rates of stillbirth and cesarean section in post-term pregnancies. CMAJ. 1999, 160: 1145-9.PubMedPubMed CentralGoogle Scholar
- Cunningham FG, Gant NF, Leveno KJ, Gilstrap LC, Hauth JC, Wenstrom KD, Editors: Williams Obstetrics. 2001, McGraw-Hill, Toronto, 21Google Scholar
- Hartley RS, Emanuel I, Hitti J: Perinatal mortality and neonatal morbidity rates among twin pairs at different gestational ages: optimal delivery timing at 37 to 38 weeks' gestation. Am J Obstet Gynecol. 2001, 184: 451-458. 10.1067/mob.2001.109399.View ArticlePubMedGoogle Scholar
- Scher AI, Petterson B, Blair E, Ellenberg JH, Grether JK, Haan E, Reddihough DS, Yeargin-Allsopp M, Nelson KB: The risk of mortality or cerebral palsy in twins: a collaborative population-based study. Pediatr Res. 2002, 52: 671-681. 10.1203/01.PDR.0000032159.88318.5B.View ArticlePubMedGoogle Scholar
- Iams JD, Creasy RK: Preterm labor and delivery. Maternal-fetal medicine: Principles and practice. Edited by: Creasy RK, Resnik R, Iams JD. 2004, Saunders, Philadelphia, 5Google Scholar
- Joseph KS: Incidence-based measures of birth, growth restriction and death can free perinatal epidemiology from erroneous concepts of risk. J Clin Epidemiol. 2004, 57: 889-97. 10.1016/j.jclinepi.2003.11.018.View ArticlePubMedGoogle Scholar
- Joseph KS: Theory of obstetrics: the fetuses at risk approach as a causal paradigm. J Obstet Gynaecol Can. 2004, 26: 953-6.View ArticlePubMedGoogle Scholar
- O'Dowd MJ, Philipp EE: The history of obstetrics and gynecology. 1994, Parthenon Publishing Group. New YorkGoogle Scholar
- Mollison PL, Engelfriet CP, Contreras M: Blood transfusion in clinical medicine. Edited by: Boston, MA. 1994, Blackwell Scientific Publications, 543-91. 9Google Scholar
- Martin JA, Hamilton BE, Sutton PD, Ventura SJ, Menacker F, Munson ML: Births: Final data for 2002. National vital statistics reports; Hyattsville, Maryland: National Centre for Health Statistics. 2003, 52 (10):Google Scholar
- Kramer MS, McLean FH, Boyd ME, Usher RH: The validity of gestational age estimation by menstrual dating in term, preterm, and postterm gestations. JAMA. 1988, 260: 3306-8. 10.1001/jama.260.22.3306.View ArticlePubMedGoogle Scholar
- Ananth C, Joseph K, Kinzler W: The influence of obstetric intervention on trends in twin stillbirths: United States, 1989–99. J Matern Fetal Neonatal Med. 2004, 15: 380-387. 10.1080/14767058410001727413.View ArticlePubMedGoogle Scholar
- Ananth CV, Joseph KS, Smulian JC: Trends in twin neonatal mortality rates in the United States, 1989 through 1999: influence of birth registration and obstetric intervention. Am J Obstet Gynecol. 2004, 190: 1313-21. 10.1016/j.ajog.2003.11.029.View ArticlePubMedGoogle Scholar
- Yuan H, Platt RW, Morin L, Joseph KS, Kramer MS: Fetal deaths in the United States, 1997 vs 1991. Am J Obstet Gynecol. 2005, 193: 489-95. 10.1016/j.ajog.2004.12.002.View ArticlePubMedGoogle Scholar
- Nelson KB: Can we prevent cerebral palsy?. N Engl J Med. 2003, 349: 1765-9. 10.1056/NEJMsb035364.View ArticlePubMedGoogle Scholar
- Williams R, Creasy R, Cunningham G, Hawes W, Norris F, Tashiro M: Fetal growth and perinatal viability in California. Obstet Gynecol. 1982, 59: 624-632.PubMedGoogle Scholar
- Battaglia F, Frazier T, Hellegers A: Birth weight, gestational age, and pregnancy outcome, with special reference to high birth weight-low gestational age infant. Pediatr. 1966, 37: 417-22.Google Scholar
- Gruenwald P: Growth of the human fetus. I. Normal growth and its variation. Am J Obstet Gynecol. 1966, 4: 1112-9.View ArticleGoogle Scholar
- Usher R, McLean F: Intrauterine growth of live-born Caucasian infants at sea-level: standards obtained from measurements in 7 dimensions of infants born between 25 and 44 weeks gestation. J Pediatr. 1969, 74: 901-10. 10.1016/S0022-3476(69)80224-6.View ArticlePubMedGoogle Scholar
- David R: Population-based intrauterine growth curves from computerized birth certificates. South Med J. 1983, 76: 1401-6.View ArticlePubMedGoogle Scholar
- Ananth CV, Vintzileos AM, Shen-Schwarz S, Smulian JC, Lai Y-L: Standards of birth weight in twin gestations stratified by placental chorionicity. Obstet Gynecol. 1998, 91: 917-24. 10.1016/S0029-7844(98)00052-0.PubMedGoogle Scholar
- Brenner W, Edelman D, Hendricks C: A standard of fetal growth for the United States of America. Am J Obstet Gynecol. 1976, 126: 555-64.View ArticlePubMedGoogle Scholar
- Lawrence C, Fryer J, Karlberg J, Niklasson A, Ericson A: Modeling of reference values for size at birth. Acta Paediatr Scand. 1989, 55-69. 350 supplGoogle Scholar
- Gardosi J, Chang A, Kalyan B, Sahota D, Symonds E: Customized antenatal growth charts. Lancet. 1992, 339: 283-7. 10.1016/0140-6736(92)91342-6.View ArticlePubMedGoogle Scholar
- Amini S, Catalano P, Hirsch V, Mann L: An analysis of birth weight by gestational age using a computerized perinatal data base, 1975–1992. Obstet Gynecol. 1994, 83: 342-52.PubMedGoogle Scholar
- Zhang J, Bowes W: Birth-weight-for-gestational-age patterns by race, sex, and parity in the United states population. Obstet Gynecol. 1995, 86: 200-208. 10.1016/0029-7844(95)00142-E.View ArticlePubMedGoogle Scholar
- Arbuckle T, Wilkins R, Sherman G: Birth weight percentiles by gestational age in Canada. Obstet Gynecol. 1993, 81: 39-48.PubMedGoogle Scholar
- Maršál K, Persson P-H, Larsen T, Lilja H, Selbing A, Sultan B: Intrauterine growth curves based on ultrasonically estimated foetal weights. Acta Paediatr. 1996, 85: 843-8.View ArticlePubMedGoogle Scholar
- Beeby PJ, Bhutap T, Taylor LK: New South Wales population-based birthweight percentile charts. J Paediatr Child Health. 1996, 32: 512-8.View ArticlePubMedGoogle Scholar
- Kramer MS, Platt RW, Wen SW, Joseph KS, Allen A, Abrahamowicz M, Blondel B, Breart G, Fetal/Infant Health Study Group of the Canadian Perinatal Surveillance System: A new and improved population-based Canadian reference for birth weight for gestational age. Pediatr. 2001, 108: E35-10.1542/peds.108.2.e35.View ArticleGoogle Scholar
- Källén B: A birth weight for gestational age standard based on data in the Swedish Medical Birth Registry, 1985–1989. Eur J Epidemiol. 1995, 11: 601-6. 10.1007/BF01719316.View ArticlePubMedGoogle Scholar
- World Health Organization: Physical status: the use and interpretation of anthropometry. Report of a WHO expert committee. Technical Report Series No. 854. Geneva: WHO. 1995Google Scholar
- Lubchenco L, Hansman C, Dressler M, Boyd E: Intrauterine growth as estimated from liveborn birth weight data at 24 to 42 weeks of gestation. Pediatr. 1963, 32: 793-800.Google Scholar
- Thomson A, Billewicz W, Hytten F: The assessment of fetal growth. J Obstet Gynaecol Br Common. 1968, 75: 903-16.View ArticleGoogle Scholar
- Alexander G, Himes J, Kaufman R, Mor J, Kogan M: A United States national reference for fetal growth. Obstet Gynecol. 1996, 87: 163-8. 10.1016/0029-7844(95)00386-X.View ArticlePubMedGoogle Scholar
- Lie RT: Invited commentary: Intersecting perinatal mortality curves by gestational age-are appearances deceiving?. Am J Epidemiol. 2000, 152: 1117-1119. 10.1093/aje/152.12.1117.View ArticlePubMedGoogle Scholar
- Yerushalmy J: The relationship of parents' cigarette smoking to outcome of pregnancy – implications as to the problem of inferring causation from observed associations. Am J Epidemiol. 1971, 93: 443-456.PubMedGoogle Scholar
- Taeusch HW, Ballard RA, Gleason CA, Editors: Avery's Disease of the Newborn. 2005, Elsevier Saunders, Philadelphia, 8Google Scholar
- Yudkin PL, Wood L, Redman CWG: Risk of unexplained stillbirth at different gestational ages. Lancet. 1987, 1: 1192-1194.PubMedGoogle Scholar
- Ferguson R, Myers SA: Population study of the risk of fetal death and its relationship to birth weight, gestational age, and race. Am J Perinatol. 1994, 11: 267-272.View ArticlePubMedGoogle Scholar
- Hilder L, Costeloe K, Thilaganathan B: Prolonged pregnancy: evaluating gestation-specific risks of fetal and infant mortality. Br J Obstet Gynecol. 1998, 105: 169-173.View ArticleGoogle Scholar
- Cnattingius S, Stephansson O: The epidemiology of stillbirth. Semin Perinatol. 2002, 26: 25-30. 10.1053/sper.2002.29841.View ArticlePubMedGoogle Scholar
- Kramer MS, Liu S, Luo Z, Yuan H, Platt RW, Joseph KS: Analysis of perinatal mortality and its components: time for a change?. Am J Epidemiol. 2002, 156: 493-497. 10.1093/aje/kwf077.View ArticlePubMedGoogle Scholar
- Sairam S, Costeloe K, Thilaganathan B: Prospective risk of stillbirth in multiple-gestation pregnancies: a population-based analysis. Obstet Gynecol. 2002, 100: 638-41. 10.1016/S0029-7844(02)02174-9.PubMedGoogle Scholar
- Smith GC, Pell JP, Dobbie R: Caesarean section and risk of unexplained stillbirth in subsequent pregnancy. Lancet. 2003, 362: 779-84.Google Scholar
- Kahn B, Lumey LH, Zybert PA, Lorenz JM, Cleary-Goldman J, D'Alton ME, Robinson JN: Prospective risk of fetal death in singleton, twin, and triplet gestations: implications for practice. Obstet Gynecol. 2003, 102: 685-92. 10.1016/S0029-7844(03)00616-1.PubMedGoogle Scholar
- Cheung YB: On the Definition of Gestational-Age-specific Mortality. Am J Epidemiol. 2004, 160: 207-10. 10.1093/aje/kwh202.View ArticlePubMedGoogle Scholar
- Joseph KS, Liu S, Demissie K, Wen SW, Platt RW, Ananth CV, Dzakpasu S, Sauve R, Allen AC, Kramer MS, The Fetal and Infant Health Study Group of the Canadian Perinatal Surveillance System: A parsimonious explanation for intersecting perinatal mortality curves: understanding the effects of plurality and parity. BMC Pregnancy Childbirth. 2003, 3: 3-10.1186/1471-2393-3-3.View ArticlePubMedPubMed CentralGoogle Scholar
- Joseph KS, Demissie K, Platt RW, Ananth CV, McCarthy BJ, Kramer MS: A parsimonious explanation for intersecting perinatal mortality curves: understanding the effects of race and of maternal smoking. BMC Pregnancy Childbirth. 2004, 4: 7-10.1186/1471-2393-4-7.View ArticlePubMedPubMed CentralGoogle Scholar
- Joseph KS, Wilkins R, Dodds L, Allen VM, Ohlsson A, Marcoux S, Liston R: Customized standards of birth weight for gestational age: perinatal mortality patterns are consistent with separate standards for males and females but not for blacks and whites. BMC Pregnancy Childbirth. 2005, 5: 3-10.1186/1471-2393-5-3.View ArticlePubMedPubMed CentralGoogle Scholar
- Fell DB, Dodds L, Allen VM, Butler B, Joseph KS: Risk factors for hyperemesis requiring hospital admission during pregnancy. Obstet Gynecol. 2006, 107 (2 Pt 1): 277-84.View ArticlePubMedGoogle Scholar
- Caughey AB, Stotland NE, Escobar GJ: What is the best measure of maternal complications of term pregnancy: Ongoing pregnancies or pregnancies delivered?. Am J Obstet Gynecol. 2003, 189: 1047-52. 10.1067/S0002-9378(03)00897-4.View ArticlePubMedGoogle Scholar
- Caughey AB, Musci TJ: Complications of term pregnancies beyond 37 weeks of gestation. Obstet Gynecol. 2004, 103: 57-62.View ArticlePubMedGoogle Scholar
- Nahum GG, Stanislaw H: Ultrasonographic prediction of term birth weight: how accurate is it?. Am J Obstet Gynecol. 2003, 188: 566-74. 10.1067/mob.2003.155.View ArticlePubMedGoogle Scholar
- Lerner JP: Fetal growth and well-being. Obstet Gynecol Clin North Am. 2004, 31: 159-76. 10.1016/S0889-8545(03)00121-9.View ArticlePubMedGoogle Scholar
- Harkness UF, Mari G: Diagnosis and management of intrauterine growth restriction. Clin Perinatol. 2004, 31: 743-764. 10.1016/j.clp.2004.06.006.View ArticlePubMedGoogle Scholar
- Dodd JM, Robinson JS, Crowther CA, Chan A: Stillbirth and neonatal outcomes in South Australia, 1991–2000. Am J Obstet Gynecol. 2003, 189: 1731-6. 10.1016/S0002-9378(03)00854-8.View ArticlePubMedGoogle Scholar
- Joseph KS, Allen AC, Dodds L, Turner LA, Scott H, Liston H: The perinatal effects of delayed childbearing. Obstet Gynecol. 2005, 105: 1410-8.View ArticlePubMedGoogle Scholar
- Hannah ME, Hannah WJ, Hewson SA, Hodnett ED, Saigal S, Willan AR, for the Term Breech Collaborative Group: Planned caesarean section versus planned vaginal birth for breech presentation at term: a randomized multicentre trial. Lancet. 2000, 356: 1375-83. 10.1016/S0140-6736(00)02840-3.View ArticlePubMedGoogle Scholar
- The Magpie Trial Collaborative Group: Do women with pre-eclampsia, and their babies, benefit from magnesium sulphate? The Magpie Trial: a randomized placebo-controlled trial. Lancet. 2002, 359: 1877-90. 10.1016/S0140-6736(02)08778-0.View ArticleGoogle Scholar
- Nelson KB, Grether JK: Potentially asphyxiating conditions and spastic cerebral palsy in infants of normal birth weight. Am J Obstet Gynecol. 1998, 179: 507-13. 10.1016/S0002-9378(98)70387-4.View ArticlePubMedGoogle Scholar
- MacLennan A: A template for defining a casual relation between acute intrapartum events and cerebral palsy: international consensus statement. BMJ. 1999, 319: 1054-9.View ArticlePubMedPubMed CentralGoogle Scholar
- ,: American College of Obstetricians and Gynecologists and American Academy of Pediatrics. Neonatal encephalopathy and cerebral palsy: defining the pathogenesis and pathophysiology. 2003, Washington, DC: ACOGGoogle Scholar
- Platt RW, Joseph KS, Ananth CV, Grondines J, Abrahamowicz M, Kramer MS: A proportional hazards model with time-dependent covariates and time-varying effects for analysis of fetal and infant death. Am J Epidemiol. 2004, 160: 199-206. 10.1093/aje/kwh201.View ArticlePubMedGoogle Scholar
- Joseph KS, Allen AC, Lutfi S, Murphy-Kaulbeck L, Vincer MJ, Wood E: Does the risk of cerebral palsy increase or decrease with increasing gestational age?. BMC Pregnancy Childbirth. 2003, 3: 8-10.1186/1471-2393-3-8.View ArticlePubMedPubMed CentralGoogle Scholar
- Kramer MS, Kierans W, Liu S, Luo ZC, Platt R, Wilkins R, Joseph KS: A new analytic approach to distinguish physiologic vs pathologic variations in fetal growth. Annual meeting of the Society for Pediatric and Perinatal Epidemiology;. 2004, [http://www.sper.org/Preliminary_Program2004.pdf]June ; Salt Lake City, Utah. Abstract Poster I – 80Google Scholar
- Miettinen OS: Theoretical epidemiology: Principles of occurrence research in medicine. 1985, John Wiley & Sons. Toronto, 11-12.Google Scholar
- Joseph KS: Form should follow function in epidemiologic modeling: Author's response (let). J Clin Epidemiol. 2005, 58: 965-6. 10.1016/j.jclinepi.2005.02.013.View ArticleGoogle Scholar
- Liu S, Joseph KS, Kramer MS, Allen AC, Sauve R, Rusen ID, Wen SW, Fetal and Infant Health Study Group of the Canadian Perinatal Surveillance System: Relationship of prenatal diagnosis and pregnancy termination to overall infant mortality in Canada. JAMA. 2002, 287: 1561-7. 10.1001/jama.287.12.1561.View ArticlePubMedGoogle Scholar
- Boulvain M, Stan C, Irion O: Membrane sweeping for induction of labour. Cochrane Database Syst Rev. 2001, CD000451-2Google Scholar
- Kayani SI, Walkinshaw SA, Preston C: Pregnancy outcome in severe placental abruption. BJOG. 2003, 110: 679-83. 10.1046/j.1471-0528.2003.02088.x.View ArticlePubMedGoogle Scholar
- Crowley P: Interventions for preventing or improving the outcome of delivery at or beyond term. (Cochrane Review). The Cochrane Library. 2004, Chichester, UK: John Wiley & Sons, Ltd, 3Google Scholar
- Churchill D, Duley L: Interventionist versus expectant care for severe pre-eclampsia before term. (Cochrane Review). The Cochrane Library. 2004, Chichester, UK: John Wiley & Sons, Ltd, 3Google Scholar
- Joseph KS, Young DC, Dodds L, O'Connell CM, Allen VM, Chandra S, Allen AC: Changes in maternal characteristics and obstetric practice and recent increases in primary cesarean delivery. Obstet Gynecol. 2003, 102: 791-800. 10.1016/S0029-7844(03)00620-3.PubMedGoogle Scholar
- Salihu HM, Shumpert MN, Slay M, Kirby RS, Alexander GR: Childbearing beyond maternal age 50 and fetal outcomes in the United States. Obstet Gynecol. 2003, 102: 1006-14. 10.1016/S0029-7844(03)00739-7.PubMedGoogle Scholar
- The pre-publication history for this paper can be accessed here:http://www.biomedcentral.com/1471-2393/7/4/prepub
This article is published under license to BioMed Central Ltd. This is an Open Access article distributed under the terms of the Creative Commons Attribution License (http://creativecommons.org/licenses/by/2.0), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.