This article has Open Peer Review reports available.
The global network antenatal corticosteroids trial: impact on stillbirth
- Robert L. Goldenberg1, 18Email author,
- Vanessa R. Thorsten2,
- Fernando Althabe3,
- Sarah Saleem4, 1,
- Ana Garces5,
- Waldemar A. Carlo6,
- Omrana Pasha4,
- Elwyn Chomba7,
- Shivaprasad Goudar8,
- Fabian Esamai9,
- Nancy F. Krebs10,
- Richard J. Derman11,
- Edward A. Liechty12,
- Archana Patel13,
- Patricia L. Hibberd14,
- Pierre M. Buekens15,
- Marion Koso-Thomas16,
- Menachem Miodovnik16,
- Alan H. Jobe17,
- Dennis D. Wallace2,
- José M. Belizán3 and
- Elizabeth M. McClure2
© Goldenberg et al. 2016
Received: 3 November 2015
Accepted: 5 May 2016
Published: 2 June 2016
Antenatal corticosteroids are commonly used to reduce neonatal mortality, but most research to date has been in high-resource settings and few studies have evaluated its impact on stillbirth. In the Antenatal Corticosteroids Trial (ACT), a multi-country trial to assess impact of a multi-faceted intervention including antenatal corticosteroids to reduce neonatal mortality associated with preterm birth, we found an overall increase in 28-day neonatal mortality and stillbirth associated with the intervention.
The ACT was a cluster-randomized trial conducted in 102 clusters across 7 research sites in 6 countries (India [2 sites], Pakistan, Zambia, Kenya, Guatemala and Argentina), comparing an intervention to train birth attendants at all levels of the health system to identify women at risk of preterm birth, administer corticosteroids and refer women at risk. Because of inadequate gestational age dating, the <5th percentile birth weight was used as a proxy for preterm birth. A pre-specified secondary outcome of the trial was stillbirth.
After adjusting for the pre-trial imbalance in stillbirth rates, the ACT intervention was associated with a non-significant increased risk of stillbirth (aRR 1.08, 95 % CI, 0.99–1.17, p–0.073). Additionally, the stillbirth rate was higher in the term births (1.20 95 % CI 1.06–1.37, 0.004) and among those with signs of maceration (RR 1.18 (1.04–1.35), p = 0.013) in the intervention vs. control clusters. Differences in obstetric care favored the control clusters and maternal infection was likely more common in the intervention clusters.
In this pragmatic trial, limited data were available to identify the causes of the increase in stillbirths in the intervention clusters. A higher rate of stillbirth in the intervention clusters prior to the trial, differences in obstetric care and an increase in maternal infection are potential explanations for the observed increase in stillbirths in the intervention clusters during the trial.
The Antenatal Corticosteroid Trial (ACT) was a cluster randomized trial performed in 7 sites in 6 low and middle income countries (LMIC) [1, 2]. The primary outcomes for that trial were to determine whether a multicomponent intervention increased the administration of antenatal corticosteroids (ACS) in the women at risk of preterm birth and then reduced neonatal mortality among that group. The primary outcome of neonatal mortality outcome was assessed among infants born at less than the site specific 5th percentile birth weight and was used as a surrogate measure for preterm birth. The intervention increased ACS use in the treatment clusters (46 % vs.10 % in <5th percentile births), but being in the intervention clusters was not associated with an improvement in neonatal mortality in the < 5th percentile infants . An unexpected finding was that neonatal mortality was higher overall in the intervention clusters, with the excess mortality occurring in infants born at ≥25th percentile site-specific birth weight.
A pre-specified secondary outcome was the stillbirth rate, which was higher in the intervention clusters compared to the control clusters . In this paper, we explore potential mechanisms which might have resulted in the higher stillbirth rate in the intervention clusters. Of note, ACT was a “pragmatic” trial and not designed to evaluate mechanisms leading to specific pregnancy outcomes, especially those such as stillbirth that were not a primary endpoint. We also emphasize that compared to prior trials demonstrating efficacy of ACS which were all individually randomized and conducted in in high and some middle income country hospitals with good obstetric and neonatal care, this cluster randomized trial enrolled more than 100,000 subjects in countries where half the women delivered at home or in low-level community clinics [3, 4].
The hospitals in these areas rarely provided comprehensive obstetric or intensive newborn services and rarely monitored the fetuses during labor . During the time that ACT was initiated, ultrasound gestational age dating was generally unavailable for women in these sites. For that reason, the target group for the primary neonatal outcome was not determined by gestational age, but by a birth weight < 5th percentile for babies born at that site. Because placental examinations and autopsies were not available, little data are available to assess the causes of the stillbirths. Nevertheless, because of the unexpected excess of stillbirths in the intervention compared to the control clusters during the ACT trial, we used available data to explore potential reasons for the higher rate of stillbirths in the intervention clusters.
This is a secondary analysis of data collected during the ACT study focusing on stillbirths. A stillbirth was defined as a baby born at ≥500 g or an estimated 20 weeks gestational age without a heartbeat, respirations or signs of movement . ACT was a cluster-randomized trial undertaken in specified geographic clusters each with approximately 500 births per year in sites in Argentina, Guatemala, Kenya, Zambia, Pakistan, and in Belgaum and Nagpur, India. The study intervention and methods are described in detail elsewhere . In brief, the study clusters were defined by each site and then randomized by the data center, RTI International (RTI). To randomize clusters, RTI created strata based on the study site and neonatal mortality rates using an ongoing registry; however the stillbirth rates in the individual clusters were not compared prior to the trial nor considered in the randomization process. The ACT outcome data were collected independently of the intervention team by trained registry administrators (RAs) in a prospective maternal and newborn health (MNH) registry, which registered pregnant women residing within the study clusters and recorded their outcomes. These included all deliveries, regardless of location in home, clinic or hospital. In addition, in the ACT intervention clusters, trained staff at each site collected process data on the use of ACS. The study was overseen by a research team at each of the study sites and a central study steering committee.
All health providers in intervention clusters were trained to identify women presenting before 36 weeks’ gestation with signs of labor, preterm premature rupture of membranes, pre-eclampsia or eclampsia, and obstetric hemorrhage as at high risk of preterm birth and potential candidates for ACS. Providers were trained to assess gestational age by use of an algorithm that included last menstrual period (LMP) and estimated delivery date, or uterine height if neither the LMP nor estimated delivery date were known. Uterine height was measured using a color-coded tape that was developed and validated to measure uterine height, with a red zone indicating an estimated gestational age younger than 36 weeks and 0 days . Ultrasound was considered to be the best estimate for gestational age determination, but was rarely available. Posters were displayed at facilities in the intervention group and discs were designed and distributed to calculate gestational age on the basis of LMP or estimated delivery date. The posters, discs and tapes also served as reminders about signs of risk. This gestational age assessment was used to determine if a woman was at high risk for preterm birth. For women determined to be eligible, providers were trained to provide one course of ACS (dexamethasone).
For intervention and control clusters, stillbirths were classified as <5th percentile based on measured birth weight and estimated weights by clinical assessment when measured weights were missing being less than the site-specific cut off. Those without any measure of birth weight were coded as <5th percentile. Additionally, site-specific birth weight percentile bands and broad birth weight groups were determined from measured and estimated birth weights collected by the RAs. If a stillbirth did not have a measured weight, estimated weights were used when they fit in one of the percentile bands or otherwise was recorded as missing. Preterm delivery (<37 weeks vs ≥ 37 weeks) was determined by an algorithm which used the estimated delivery date and last menstrual period recorded by the RAs, and site-specific 95th percentile for birth weight at 36 weeks.
Stillbirths in low-income countries are often classified by maceration or fresh status . The RAs were trained to determine maceration status using pictures of macerated stillbirths (e.g., peeling skin) in training sessions. Fresh stillbirths are generally considered to have occurred within 12 h of delivery and generally during the intrapartum period. Most of these deaths are believed to be due to asphyxia occurring during labor. Macerated stillbirths are generally considered to have died before labor . The deaths in macerated fetuses are considered due to a variety of causes including infection .
In the analysis phase, suspected maternal infection was assessed by using a composite of process outcomes including maternal receipt of antibiotics plus hospital admission or referral, and receipt of intravenous fluids, surgery, or other treatment related to infection . Additionally, women with postpartum signs and symptoms of severe sepsis with admission to hospital or sepsis as the primary cause of maternal death were included. The definition also included evidence of antepartum or post-partum infection for mothers with infants with a birth weight less than 2500 g. This algorithm was not used clinically.
The trial population included all births, whether stillborn or live born. The trial period included births between October 2011 and March 2014, depending on each site’s 18-month enrollment period, with most births occurring in 2012 and 2013. Because the MNH registry was initiated prior to the trial, stillbirth rates and process data were available in each cluster for at least a year prior to the initiation of the study . The pretrial period occurred in 2010 and 2011 (four clusters in Belgaum, India were added in 2011).
Generalized linear models were used to evaluate the relationship between covariates and the outcomes of interest and to develop point and interval estimates of relative risk (RR) associated with these risk factors. Generalized estimating equations were used to account for the correlation of outcomes within cluster to develop appropriate confidence intervals. Models were log binomial when possible, otherwise Poisson models were utilized. Models were adjusted for randomization strata. All analyses were done by RTI International with SAS versions 9.3 and 9.4 (SAS Institute, Cary, NC, USA).
The ACT trial was reviewed and approved by the ethics committees at each site, the World Health Organization and the NICHD. All women provided informed consent prior to participation. Trial registration was at clinicaltrials.gov (NCT01084096).
Stillbirth rates during the pretrial (2010) and trial periods by ACT intervention group and site
RR (95 %)b
All babies, N
Stillbirths, N (Rate/1000)a
<5th percentile for weight babies, N
<5th percentile stillbirths, N (Rate/1000)a
1.15 (1.04, 1.28)
RR (95 %)b
All babies, N
Stillbirths, N (Rate/1000)a
Adjusted for pretrial SB rate
<5th percentile for weight babies, N
<5th percentile stillbirths, N (Rate/1000)a
Adjusted for pretrial <5th percentile for weight SB rate
0.97 (0.89, 1.05)
Prior to the trial, the stillbirth rate in the <5th percentile births was 310.6 per 1000 in the intervention group and 272.6 per 1000 births in the control group (RR 1.15, 95 % CI 1.04–1.28, p = 0.008) (Table 1). During the trial, the stillbirth rate in the intervention clusters in the <5th percentile births was 228.9/1000 births while in the < 5th percentile births in the control clusters, the stillbirth rate was 246.6/1000 births (RR 0.99, 95 % CI 0.90–1.09, p = 0.813). Adjusting for the pretrial stillbirth rate and randomization strata, the stillbirth risk among the <5th percentile births remained similar (RR 0.97, 95 % CI 0.89–1.05, p = 0.409).
We evaluated the stillbirth rates between the intervention and control groups by site in the pretrial and trial periods. As shown in Table 1, the stillbirth rates fell substantially in all sites but Kenya from the pretrial to the trial period. The overall reductions in stillbirth rates were by 5.0/1,000 births in the intervention clusters and 3.3/1,000 births in the control clusters. During the trial period, 5 of the 7 sites including Pakistan, Belgaum, Zambia, Kenya and Guatemala had a higher stillbirth rate in the intervention compared to the control clusters, while Nagpur and Argentina had lower stillbirth rates in the intervention clusters. The higher stillbirth rates in the intervention clusters in Pakistan (49.7 vs. 42.2 per 1000, p = 0.009) and in Zambia (22.9 vs.15.9 per 1000, p = 0.020) were statistically significant as was the lower stillbirth rate in the intervention clusters compared to the control clusters in Argentina (11.8 vs. 13.4 per 1000, p = 0.006). In the <5th percentile births, Zambia had a higher stillbirth rate in the intervention clusters that was nearly significant (238.5 vs. 193.9 per 1000, p = 0.0561 while Kenya had a lower stillbirth rate in the intervention clusters that also was nearly significant (184.0 vs 250.0 per 1000, p = 0.066).
Stillbirth characteristics by ACT intervention group
RR (95 % CI)d
Stillbirths (SB), N
Male SB rate, N (Rate/1000)
1.10 (0.99, 1.22)
Female SB rate, N (Rate/1000)
1.08 (0.96, 1.22)
Birth weight percentile b, N (% of stillbirths)
Birth weight categorizedc, N
< 1000 g SB rate, N (Rate/1000)
0.93 (0.83, 1.05)
1000–1499 g SB rate, N (Rate/1000)
1.22 (1.10, 1.36)
1500–2499 g SB rate, N (Rate/1000)
0.91 (0.78, 1.06)
2500+ g SB rate, N (Rate/1000)
1.18 (1.04, 1.33)
Preterm SB rate, N (Rate/1000)
0.93 (0.83, 1.04)
Term SB rate, N (Rate/1000)
Macerated, N (% of stillbirths)
1.18 (1.04, 1.35)
Women in the treatment group identified by the intervention as high risk who received steroids and delivered a stillborn baby
Time since 1st dose to delivery, N (%)
Less Than 2 Days
More than one month
Table 2 also provides the birth weight percentile and birth weight group distributions in the intervention and control clusters among the stillbirths. Site specific birth weight percentile bands could not be categorized for 244 (19 %) of intervention babies and 250 (20 %) of control babies. Stillbirths in the treatment and control groups were similarly distributed in the 25th - 49th and 50th – 74th birth weight percentile bands. Among the intervention group there were more stillbirths in the 5th - 24th percentile band and the 75th or greater percentile band than the control group. However, when adjusted by randomization strata, these differences in the distribution by treatment group were not statistically significant (p = 0.2114). There were fewer stillbirths missing from the broad birth weight groups (3 % of the intervention and 4 % of the control stillbirths did not have a measured or estimated birth weight). When compared to the control group, the intervention cluster stillbirth rates were lower, but not significantly so, in the <1000 g (p = 0.2385) and 1,500-2,499 g (p = 0.2177) groups and significantly higher in the 1,000-1,499 g (p = 0.0003) and ≥2,500 g groups (p = 0.0078).
Conceding that our gestational age data were not optimal, we nevertheless attempted to evaluate and compare stillbirth rates by whether the fetuses in the intervention and control clusters were preterm or term. When the babies were divided into term and preterm groups, stillbirth rates were lower but not significantly so in births classified as preterm (116.6 vs 127.8 per 1000 births (RR 0.93, 95 % CI 0.83, 1.04, p = 0.182) (Table 2) and significantly higher in births classified as term in the treatment vs control clusters, 12.8 vs 10.6 per 1000 births (RR 1 · 20, 95 % CI 1 · 06, 1 · 37, p = 0.004).
Considering these three analyses, the most consistent finding was a higher rate of stillbirth in the heavier, and most likely term fetuses in the intervention clusters. The results for the lighter less mature infants were inconsistent, but some of the results suggest that there may have been a small reduction in stillbirths in some of the low birth weight and preterm groups in the intervention clusters.
Macerated and non-macerated stillbirths by ACT intervention group
Characteristic, N (%)
All stillbirths, N
Birth weight percentilea
Birth weight categorizedb
< 1000 g
We also explored when the stillbirths occurred in relationship to the timing of the first ACS injection, but had this information only for the intervention clusters. Table 2 shows that half of the mothers of stillbirths who received ACS delivered within the first week after the ACS injection, (31 % at <2 days) with about a quarter of the deliveries each occurring at 8–28 days and > 28 days. Thus, many of the mothers of stillbirths delivered in relatively close proximity to receiving the ACS dose. Conversely, about half delivered a week or more after the ACS administration.
Factors related to process of care by ACT intervention group among all births
Any antenatal care
Number of antenatal visits
Data not collected during pretrial period
Trimester of 1st antenatal visit
Administration of diagnosis tests or preventive care
Syphilis or HIV test
Tetanus toxoid vaccine
We did not have data to evaluate whether fetal infection was more common in stillbirths in the control or intervention clusters since autopsies or placental examinations were not performed. However, as in the primary paper, we had data to evaluate potential infection in the mothers. Suspected maternal infection was reported in 2.5 % of women in the intervention clusters and 1.7 % in the control clusters (OR 1 · 45, 95 % CI 1 · 33–1 · 58, p < 0 · 0001). Among women who delivered <5th percentile infants, the suspected maternal infection was reported in 10.0 % of the women in the intervention clusters and 6.4 % of women in the control clusters (OR 1 · 67, 95 % CI 1 · 33–2 · 09, p < 0 · 0001). Thus, there appeared to be a greater incidence of maternal infection in the intervention clusters.
Mothers of stillbirths were also more likely to be classified as having a suspected maternal infection (207/2,526 (8.2 %) versus 1,867/97,211 (1.9 %) of mothers with a live birth. Among mothers with stillbirth, 114/1,280 (8.9 %) in the treatment group and 93/1,153 (7.5 %) in the control group experienced suspected maternal infection. Three of the sites (Argentina [12.0 % vs 6.7 %], Belgaum [7.8 % versus 5.3 %] and Nagpur [11.7 % vs 5.0 %] showed modest higher risk of having a suspected maternal infection in the treatment arm. The other four sites had less than a 1.2 % difference in risk between the arms withGuatemala and Kenya having slightly higher risk in the treatment arm and Zambia and Pakistan having slightly higher risk in the control arm. Because the number of events was relatively small and all sites had heterogeneity of effects across randomization strata, no formal inference of overall or within site differences was conducted and an overall odds ratio was not calculated.
Stillbirth rates by ACS administrationa and ACT intervention group and site
Stillbirths ≥ 20 weeks GA or ≥ 500 g, N (Rate/1000)
Stillbirths ≥ 20 weeks GA or ≥ 500 g, N (Rate/1000)
We explored potential reasons for the higher stillbirth rate in the intervention clusters compared to the control clusters in the ACT trial. As a secondary analysis of a non-primary outcome in a trial not designed for this purpose, the results cannot be considered definitive, but may suggest further research directions.
The higher stillbirth rate in intervention clusters was found in five of the seven sites. Although the overall differences in stillbirth rates between the intervention and control clusters were significant, the results were not in the same direction at all sites. Further exploration of the reasons for site-specific differences in stillbirth rates therefore may be warranted. Stillbirth rates were higher in the intervention clusters to the same degree in male and female fetuses so differential impact by gender does not appear to be part of the explanation for these findings. The increase in stillbirths occurred in fetuses labeled as macerated and not in fresh stillbirths. This finding suggests that the higher stillbirth rate in the intervention clusters did not occur during the labor and delivery process, but instead occurred in the antenatal period. Since about 50 % of the mothers of stillbirths delivered within a week after receiving the ACS injection, this suggests, but does not prove, that some of the increase in stillbirths associated with being in the intervention clusters occurred within days after receiving the ACS injection, but not during labor. On the other hand, about 50 % of the mothers of stillbirths delivered more than a week following receipt of ACS.
Because of the relatively poor gestational age ascertainment at the sites during the trial, the results regarding gestational age and stillbirth rates should be interpreted cautiously. Nevertheless, the stillbirth rate was higher in the intervention clusters in fetuses who appeared to be term compared to preterm, in fetuses ≥25th percentile birth weight, and in fetuses ≥ 2500 g. These consistent results strongly suggest that there were higher stillbirth rates in the heavier more mature fetuses in the intervention clusters. The results for the smaller and earlier gestational age fetuses are less consistent. Since there were fewer stillbirths in the intervention clusters in the < 5th percentile births, in the < 1000 g births and in the 1500 to 2499 g births and in fetuses categorized as preterm, it is unlikely the intervention was associated with a higher stillbirth rate in smaller earlier gestational age stillbirths, and there may have been a small reduction in the stillbirth rates in these groups.
The reason mothers of fetuses who received ACS delivered outside the targeted window or even at term are unknown. One possible explanation is that the gestational age dating was often inaccurate, and the care givers who determined use of ACS were often inexperienced and poorly trained. Another explanation, and a common finding in many of the published ACS trials, is that a significant proportion of ACS recipients were in the appropriate gestational age interval when they received the ACS injection, but delivered later in their pregnancy [11, 12]. We expect that both explanations account for the fact that many women in this trial who received ACS delivered heavier and older gestational age infants.
We have little data to help us explain the cause for the higher stillbirth rate in the intervention clusters. From the primary paper we know that women in the intervention arm likely had more infections than women and neonates in the control clusters . We also know that the increase in stillbirths in the intervention compared to control clusters was associated with a higher rate of maceration, suggesting that asphyxia during labor was not the cause of the higher stillbirth rate. Since aside from asphyxia and congenital anomalies, infection is the primary cause of stillbirths, it is conceivable that the higher rate of stillbirths associated with being in the intervention clusters is in part related to increased infection. Proving that this is the explanation for the higher rate of stillbirths in the intervention clusters is not possible from the available data, but any future study of ACS in LIC settings should collect data related to maternal and fetal infection status.
There were differences in obstetric care between the intervention and control clusters and these differences were found in both the pretrial and trial period. In the pretrial period these differences were also associated with a difference in stillbirth rates between the intervention and control clusters. Therefore, our data do not allow us to rule out the possibility that part of the differences in stillbirth rates between the intervention and control clusters prior to and during the trial were due to differences in obstetric care.
Most randomized trials of ACS have not reported stillbirth rates and those that have reported stillbirth rates generally report stillbirths that occurred in the week following ACS administration or in preterm newborns. However, a meta-analysis of women who received ACS and delivered later than 7 days after ACS administration showed significant increases in both perinatal deaths and in chorioamnionitis in the treatment group . Stillbirths were increased, but not significantly so. Thus, there is a precedent in the literature that ACS given to women who ultimately deliver outside the one-week window of likely benefit for neonatal outcomes may have an increase in infection and stillbirth associated with ACS administration. Because so many women in this trial delivered outside the 7-day window, and delivered more mature and heavier infants, these factors may explain some of the ACT study stillbirth findings. However, more likely, the differences in stillbirth rates between the intervention and control clusters in the ACT trial period are explained at least in part by the differences in health care that existed prior to the ACT study and continued throughout the study.
In summary, in the ACT trial there was a small but significantly higher rate of stillbirths among women in the intervention clusters. The increase was seen in 5 of the 7 sites, and was not consistent across the study. Differences in care between the intervention and control clusters may explain part or all of the higher stillbirth rate in the intervention clusters, but this possibility cannot be proven from the available data. It is also possible that differences in unmeasured maternal characteristics such as syphilis or malaria played a role. The higher stillbirth rate in the intervention clusters was similar in male and female fetuses. The higher stillbirth rate in the intervention clusters was apparent only in the larger and term fetuses. There was no consistent increase in stillbirths in the intervention clusters in the lighter more preterm infants and there may have been a small reduction in stillbirths in some birth weight and gestational age groups. Because of the poor gestational age dating available for those participating in the ACT trial, we can make no definitive statement about the impact of the intervention on stillbirth rates in smaller and earlier gestational age fetuses. Finally, data related to causation are limited, but suggest that fetal asphyxia is not likely to explain our findings. Instead, our data suggest that infection may explain some of the observed higher rate of stillbirths in the intervention clusters. The meta-analysis of individually randomized ACS trials showing an increase in infection and perinatal mortality in women delivering more than 7 days after receiving ACS lends credence to this hypothesis . Nevertheless, it appears that the higher stillbirth rate in the intervention clusters preceded the study and was coincident with differences in obstetric care between the intervention and control clusters. We also emphasize that the difference in stillbirth rates between the intervention and control clusters was small and although statistically significant could have occurred by chance.
This trial was funded through grants from the Eunice Kennedy Shriver National Institute of Child Health and Human Development (U01 HD058322, U01 HD040477, U01 HD043464, U01 HD040657, U01 HD042372, U01 HD040607, U01 HD058326, U01 HD040636). Additional support was also provided by the Bill and Melinda Gates Foundation (FA, KK, JMB)
RLG, FA, PMB and JMB conceived of the study. FA, VT, EMM, PLH, RLG, WAC, AG, AP, OP, EC, NFK, SG, RJD, FE, EAL, NIH, SM, DDW, MKT, AHJ, PMB, and JMB participated in its design and coordination and monitoring the study. RLG, EMM wrote the manuscript with FA, VT, DDW and JMB. All authors read and approved the final manuscript.
The authors declare that they have no competing interests.
Open AccessThis article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.
- Althabe F, Belizán JM, McClure EM, Hemingway-Foday J, Berrueta M, Mazzoni A, et al. A population-based, multifaceted strategy to implement antenatal corticosteroid treatment versus standard care for the reduction of neonatal mortality due to preterm birth in low-income and middle-income countries: the ACT cluster-randomised trial. Lancet. 2015;385(9968):629–39.View ArticlePubMedGoogle Scholar
- Althabe F, Belizan J, Mazzoni A, Berrueta M, Hemingway-Foday J, Koso-Thomas M, et al. Antenatal corticosteroids trial in preterm births to increase neonatal survival in developing countries: study protocol. Reprod Health. 2012;9:22.Google Scholar
- Mwansa-Kambafwile J, Cousens S, Hansen T, Lawn JE. Antenatal steroids in preterm labour for the prevention of neonatal deaths due to complications of preterm birth. Int J Epidemiol. 2010;39 suppl 1:i122–33.View ArticlePubMedPubMed CentralGoogle Scholar
- Roberts D, Dalziel S. Antenatal corticosteroids for accelerating fetal lung maturation for women at risk of preterm birth. Cochrane Database Syst Rev. 2006;3, CD004454.PubMedGoogle Scholar
- Manasyan A, Saleem S, Koso-Thomas M, Althabe F, Pasha O, Chomba E, Goudar SS, Patel A, Esamai F, Garces A, Kodkany B, Belizan J, McClure EM, Derman RJ, Hibberd P, Liechty EA, Hambidge KM, Carlo WA, Buekens P, Moore J, Wright LL, Goldenberg RL, EmONC Trial Group. Assessment of obstetric and neonatal health services in developing country health facilities. Am J Perinatol. 2013;30(9):787–94.View ArticlePubMedPubMed CentralGoogle Scholar
- McClure EM, Saleem S, Goudar SS, Moore JL, Garces A, Esamai F, et al. Stillbirth rates in low-middle income countries 2010–2013: a population-based, multi-country study from the Global Network. Reprod Health. 2015;12 Suppl 2:S7.View ArticlePubMedPubMed CentralGoogle Scholar
- Althabe F, Berrueta M, Hemingway-Foday J, Mazzoni A, Bonorino CA, Gowdak A, Gibbons L. A color-coded tape for uterine height measurement: a tool to identify preterm pregnancies in low resource settings. PLoS One. 2015;10(3), e0117134.View ArticlePubMedPubMed CentralGoogle Scholar
- Goldenberg RL, McClure EM, Kodkany B, Wembodinga G, Pasha O, Esamai F, Tshefu A, Patel A, Mabaye H, Goudar S, Saleem S, Waikar M, Langer A, Bose CL, Rubens CE, Wright LL, Moore J, Blanc A. A multi-country study of the “intrapartum stillbirth and early neonatal death indicator” in hospitals in low-resource settings. Int J Gynaecol Obstet. 2013;122(3):230–3.View ArticlePubMedPubMed CentralGoogle Scholar
- Turnbull E, Lembalemba MK, Guffey MB, Bolton-Moore C, Mubiana-Mbewe M, Chintu N, et al. Causes of stillbirth, neonatal death and early childhood death in rural Zambia by verbal autopsy assessments. Trop Med Int Health. 2011;16(7):894–901. MNH.View ArticlePubMedPubMed CentralGoogle Scholar
- Bose CL, Bauserman M, Goldenberg RL, Goudar SS, McClure EM, Pasha O, Carlo WA, Garces A, Moore JL, Miodovnik M, Koso-Thomas M. The global network maternal newborn health registry: a multi-national, community-based registry of pregnancy outcomes. Reprod Health. 2015;12 Suppl 2:S1.View ArticlePubMedPubMed CentralGoogle Scholar
- Morken NH, Källen K, Jacobsson B. Predicting risk of spontaneous preterm delivery in women with a singleton pregnancy. Paediatr Perinat Epidemiol. 2014;28(1):11–22.View ArticlePubMedGoogle Scholar
- Goldenberg RL, Iams JD, Mercer BM, Meis PJ, Moawad AH, Copper RL, et al. The preterm prediction study: the value of new vs standard risk factors in predicting early and all spontaneous preterm births. NICHD MFMU Network. Am J Public Health. 1998;88(2):233–8.View ArticlePubMedPubMed CentralGoogle Scholar
- McLaughlin KJ, Crowther CA, Walker N, Harding JE. Effects of a single course of corticosteroids given more than 7 days before birth: a systematic review. Aust N Z J Obstet Gynaecol. 2003;43(2):101–6.View ArticlePubMedGoogle Scholar