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Introduction: Our study evaluated how a history of stillbirth in either of the first two pregnancies affects the risk of having a stillbirth or other adverse pregnancy outcomes in the third subsequent pregnancy. Material and Methods: We used the Swedish Medical Birth Register to define a population‐based cohort of women who had at least three singleton births from 1973 to 2012. The exposure of interest was a history of stillbirth in either of the first two pregnancies. The primary outcome was subsequent stillbirth in the third pregnancy. Secondary outcomes included: preterm birth, preeclampsia, placental abruption and small‐for‐gestational‐age infant. Adjusted logistic regression was performed including maternal age, body mass index, smoking, diabetes and hypertension. A sensitivity analysis was performed excluding stillbirths associated with congenital anomalies, pregestational and gestational diabetes, hypertension and preterm stillbirths. Results: The study contained data on 1 316 175 births, including 8911 stillbirths. Compared with women who had two live births, the highest odds of stillbirth in the third pregnancy were observed in women who had two stillbirths (adjusted odds ratio [aOR] 11.40, 95% confidence interval [95% CI] 2.75–47.70), followed by those who had stillbirth in the second birth (live birth–stillbirth) (aOR 3.59, 95% CI 2.58–4.98), but the odds were still elevated in those whose first birth ended in stillbirth (stillbirth–live birth) (aOR 2.35, 1.68, 3.28). Preterm birth, pre‐eclampsia and placental abruption followed a similar pattern. The odds of having a small‐for‐gestational‐age infant were highest in women whose first birth ended in stillbirth (aOR 1.93, 95% CI 1.66–2.24). The increased odds of having a stillbirth in a third pregnancy when either of the earlier births ended in stillbirth remained when stillbirths associated with congenital anomalies, pregestational and gestational diabetes, hypertension or preterm stillbirths were excluded. However, when preterm stillbirths were excluded, the strength of the association was reduced. Conclusions: Even when they have had a live‐born infant, women with a history of stillbirth have an increased risk of adverse pregnancy outcomes; this cannot be solely accounted for by the recurrence of congenital anomalies or maternal medical disorders. This suggests that women with a history of stillbirth should be offered additional surveillance for subsequent pregnancies. [ABSTRACT FROM AUTHOR]

Objective To compare causes of stillbirth in preterm and term pregnancies. Design Cohort study. Setting All delivery wards in Stockholm, 1998-2009. Population Stillbirths from singleton pregnancies of gestational age ≥22+0 ( n = 1089) extracted from a web-based database including all stillbirths in the major Stockholm area since 1998. Methods The parents of the stillborns were all offered an extensive standardized investigation. The causes of death were assigned in a perinatal audit using the Stockholm classification of stillbirth. Singleton stillbirths were divided into preterm (gestational week 22+0-36+6) and term/post-term (gestational week ≥37+0). The term/post-term group was subdivided into term (gestational week 37+0-40+6) and post-term stillbirths (gestational week ≥41+0). Main outcome measure Causes of stillbirth at different gestational ages. Results A higher proportion of placental abruption and preeclampsia/hypertension was seen in preterm stillbirths compared with term/post-term stillbirths, which instead had a higher proportion of umbilical cord complications and infection. Infection was more common in post-term than term stillbirths (46.5 vs. 19.8%, p < 0.001). Conclusion Increased knowledge of causes of stillbirth in different gestational ages may be valuable in developing strategies for prevention of fetal death. The high proportion of infection in post-term stillbirths could be clinically important and warrants further studies. [ABSTRACT FROM AUTHOR]

Objective: To generate a regression equation for the nuchal translucency (NT) median for the Swedish population and compare this with other median values. Setting: Eight Swedish hospitals. Sample: The data set included 20 887 unaffected fetuses. Methods: Calculation and generation of an NT centile chart for the Swedish population. Results: The NT centiles for crown-rump length (CRL) from 45 to 84 mm were calculated and compared with the medians from Glasgow, from the Fetal Medicine Foundation (FMF, London, UK; FMF-original) and those published recently (FMF-new). The NT medians cease to increase at CRLs between 70 and 75 mm. The Swedish, FMF-new and Glasgow medians followed the same pattern, but the Glasgow NT median curve was systematically lower by around 20%. Swedish, FMF-new and Glasgow medians differed in shape from the FMF-original medians, which continuously increase throughout the whole range of CRLs. Conclusions: Our results demonstrate that there are substantial differences in the NT medians and centiles between countries. [ABSTRACT FROM AUTHOR]