13 May 2014: The PLOS ONE Staff (2014) Correction: Mode of Delivery and Offspring Body Mass Index, Overweight and Obesity in Adult Life: A Systematic Review and Meta-Analysis. PLOS ONE 9(5): e97827. doi: 10.1371/journal.pone.0097827 View correction
It has been suggested that mode of delivery, a potentially powerful influence upon long-term health, may affect later life body mass index (BMI). We conducted a systematic review and meta-analysis of the effect of Caesarean section (CS) and vaginal delivery (VD) on offspring BMI, overweight (BMI>25) and obesity (BMI>30) in adulthood. Secondary outcomes were subgroup analyses by gender and type of CS (in-labour/emergency, pre-labour/elective).
Using a predefined search strategy, Pubmed, Google Scholar and Web of Science were searched for any article published before 31st March 2012, along with references of any studies deemed relevant. Studies were selected if they reported birth characteristics and long-term offspring follow-up into adulthood. Aggregate data from relevant studies were extracted onto a pre-piloted data table. A random-effects meta-analysis was carried out in RevMan5. Results are illustrated using forest plots and funnel plots, and presented as mean differences or odds ratios (OR) and 95% confidence intervals.
Thirty-five studies were identified through the search, and 15 studies with a combined population of 163,753 were suitable for inclusion in the meta-analysis. Comparing all CS to VD in pooled-gender unadjusted analyses, mean BMI difference was 0·44 kg·m-2 (0·17, 0·72; p = 0·002), OR for incidence of overweight was 1·26 (1·16, 1·38; p<0·00001) and OR for incidence of obesity was 1·22 (1·05, 1·42; p = 0·01). Heterogeneity was low in all primary analyses. Similar results were found in gender-specific subgroup analyses. Subgroup analyses comparing type of CS to VD showed no significant impact on any outcome.
There is a strong association between CS and increased offspring BMI, overweight and obesity in adulthood. Given the rising CS rate worldwide there is a need to determine whether this is causal, or reflective of confounding influences.
Citation: Darmasseelane K, Hyde MJ, Santhakumaran S, Gale C, Modi N (2014) Mode of Delivery and Offspring Body Mass Index, Overweight and Obesity in Adult Life: A Systematic Review and Meta-Analysis. PLoS ONE 9(2): e87896. doi:10.1371/journal.pone.0087896
Editor: Andrew Dewan, Yale School of Public Health, United States of America
Received: August 1, 2013; Accepted: January 4, 2014; Published: February 26, 2014
Copyright: © 2014 Darmasseelane et al. This is an open-access article distributed under the terms of the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original author and source are credited.
Funding: Funding was provided by Imperial College BSc studentship. The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
Competing interests: The authors have declared that no competing interests exist.
The last twenty years have seen worldwide increases in obesity prevalence in children and adults, with the highest incidences reported in the USA and Scotland (33·8% and 30% respectively) . In England, adult obesity has risen from 16·4% to 26% between 1995 and 2010 ,  at an estimated cost to the National Health Service of >£5·1billion annually .
Concurrently, between 1990 and 2008, there has been a 100% increase in Caesarean Section (CS) births in England . The World Health Organisation (WHO) recommends that the CS rate should not exceed 15% . However many countries report higher rates; including China (60%) , Brazil (47%) , and England (23·8%) .
Adverse effects of CS on the neonate immediately post-partum are widely recognised. CS is associated with the highest rates of neonatal morbidity and mortality of all modes of delivery , with increased risk of a low 1-minute Apgar , respiratory distress, hypoglycaemia and a prolonged stay in a neonatal intensive care unit .
Controversially, it has been suggested that birth by CS predispose offspring to adverse health outcomes in childhood . A 20% increased odds of asthma and type-1 diabetes, and a 23–32% increased odds of atopic disorders have been reported. An association between CS and later-life obesity has also been postulated. A study conducted in North America, evaluating almost 200,000 adolescents, reported that children born by CS are 40% more likely to be overweight . To date studies addressing the possibility of an association between CS and adult obesity have been small and contradictory. Goldani et al  in a Brazilian cohort study of young adults aged 23–24, demonstrated that the odds of obesity are increased by 50% following birth by CS. Conversely another Brazilian study evaluating obesity in 4297 adults showed no difference by mode of delivery . A recent meta analysis published by Li et al  presented adult data from 3 studies (n = 6,807) that specifically examined the effect of mode of delivery and offspring overweight/obesity, demonstrating an adjusted pooled OR of 1.50 (95%CI 1.02, 2.20, I2 = 74%).
We aimed to perform a systematic review and meta-analysis to identify any association between mode of delivery and offspring body mass index (BMI), and risk of overweight, and obesity in adulthood. We also sought to determine if offspring age, gender and type of CS had an effect on outcomes. In contrast to Li et al  we aimed to include all cohorts reporting data on adult BMI and weight, together with mode of delivery, independent of whether or not the association between the two was studied or published.
A systematic review of studies reporting adult anthropometry (BMI, height, weight, incidence of overweight/obesity) by mode of delivery was conducted using an a priori protocol (registered on PROSPERO ) following PRISMA guidelines for reporting systematic reviews and meta-analyses .
Definition of exposure and outcomes
Outcomes studied were offspring BMI, overweight and obesity in adulthood (≥18 years). Overweight and obesity were classified according to the National Institute of Clinical Excellence categories , namely “obese” (BMI>30) and “overweight or obese” (BMI>25, including BMI>30). Type of exposure was classed as vaginal delivery (VD) (including natural, forceps and vacuum extraction) and CS, with CS groups further categorised as Pre-Labour CS (pre-labour-CS) or In-Labour CS (in-labour-CS).
A search was conducted in PubMed (http://www.ncbi.nlm.nih.gov/) for any studies published before 31st March 2012, using the following search strategy using PubMed Medical Subject Heading (MeSH) terms: “(Parturition OR Delivery, Obstetric OR Cesarean) AND (obesity OR Body Mass Index OR Overweight)”, limited to human studies. A similar search of Google Scholar (http://scholar.google.co.uk/) and Web of Knowledge (http://apps.webofknowledge.com) was also carried out using the search strategy “(caesarean OR cesarean OR caesarian OR cesarian) AND (obesity OR Body Mass Index OR Overweight) AND (Adult) AND (Offspring)”. No limits on language, country, study type or publication period were applied. Foreign language publications were translated using “Google Translate” (http://translate.google.com/).
Titles and abstracts of identified studies were independently screened by two reviewers [KD and MJH]. If abstracts were unavailable, the full text was obtained. The full texts of relevant abstracts were appraised for inclusion [KD and CG]. Any disagreement over eligibility of a study was referred to all authors. For inclusion a study must have reported either: (1) both mode of delivery and adult offspring BMI; (2) mode of delivery with long-term offspring follow-up (into adulthood) or (3) adult offspring BMI with birth characteristics. References of included studies were hand searched for relevant publications. Review articles and letters to editors were excluded after reference lists were searched. If multiple papers reported data from the same cohort, the study reporting BMI at an age closest to the median age across all studies was included.
A basic dataset was extracted from each study using a pre-piloted data collection form [KD and SS]. In studies where required data were not reported or only adjusted results provided, authors were contacted to request these [KD and MJH]. If no response was received after two emails or relevant data were unavailable, the study was excluded from the meta-analysis. Where authors were not contactable, the principal investigator of the cohort was approached. Where mean and SD for BMI was provided by gender only, combined means and SD for both genders together were calculated.
Methodological quality of each study was assessed using a modified Newcastle-Ottawa Scale  [KD and SS]; studies are scored based on population selection, study comparability and outcome (Figure S1).
Meta-analyses were carried out using the inverse-variance method for mean BMI difference and the Mantel-Haenszel method for overweight and obesity odds ratios (OR) in RevMan 5 (5.0.23) to identify any association between mode of delivery and adult BMI, overweight and obesity separately. Forest plots were created using RevMan 5 (5.0.24). Funnel plots were created and Egger's Test  performed in Stata 12 to investigate publication bias and other small-study effects. Differences between groups are provided as pooled estimated mean differences with 95% confidence interval (CI) or unadjusted OR with 95% CI.
Between study heterogeneity
Random-effects models were used throughout as it was considered unlikely that the effect of interest was the same across all studies, invalidating the main assumption for fixed-effect models. Heterogeneity (between study variation) was assessed using the chi-squared test for Cochrane's Q statistic and by calculating I2, the estimated proportion of variance in the study outcome due to heterogeneity , .
However, where heterogeneity was low (p>0·05 from the chi-squared test and I2<50%), a fixed-effects model was carried out to check the sensitivity of findings as a random effects analysis can give greater weight to smaller studies. As heterogeneity tests have low power when study numbers are small , a fixed-effects meta-analysis was not carried out for analyses with less than five studies. If I2 was 0% a fixed-effects analysis was also not carried out as results would be identical to the random-effects model.
For all random effects analyses 95% prediction intervals (PI) were calculated as this provides a useful measure of the effects we would expect to see in future studies . The prediction interval is the range in which 95% of individual study effects are expected to lie, in contrast to the confidence interval which is for the average effect across all studies. The limits are given by where is the pooled estimate of the average effect, its standard error, and the estimate of between study variance. A t distribution on k-2 degrees of freedom (where k is the number of studies) is used rather than a normal distribution because is estimated with uncertainty.
Pre-specified subgroup analyses were carried out by gender and type of CS (in-labour-CS/pre-labour-CS) for studies providing relevant data. Where a substantial difference in the magnitude of BMI difference was shown between subgroups, statistical significance was tested using meta-regression. Meta-regression was also used to determine whether study results varied with age of offspring.
If type of CS data were available for only a subgroup of studies, to confirm that any difference in results was not due to a subgroup effect, the mean BMI difference, overweight OR and obesity OR was calculated for the subgroup comparing all CS deliveries (i.e. not separated into pre-labour-CS or in-labour-CS) to VD.
The search yielded 3292 abstracts (PubMed: 1413; Google Scholar: 1850; Web of Science: 29). Google Scholar imposes a 1000 result limit, so only the first 1000 abstracts were screened. Consequently, 2442 titles and abstracts were screened for inclusion. Seventy-nine abstracts appeared relevant; through hand-searching their references a further 90 abstracts were screened of which 57 appeared relevant. A further paper was identified through external means. Duplicate datasets, and papers which on full examination evidently had not collected mode of delivery data, were removed, leaving 35 studies with apparently relevant data (Figure 1).
The relevant number of papers at each point is given.
The authors of 30 studies were contacted , , –; one cohort was contacted directly ; two cohort studies were open-access –; and in two cases we were unable to contact the authors , . Twenty-nine authors replied , , –, – of whom 13 provided additional data suitable for inclusion , , –, , .
The 1958 British Birth Cohort dataset included implausible BMI values, so limits were imposed (excluding subjects with BMI>200 kg·m−2 and BMI<10 kg·m−2). Mean (SD) BMI was calculated following exclusion of these implausible data.
The 1924 Helsinki Birth Cohort  had a small CS group (n = 5), so was only included in the overall meta-analyses. The single gender studies of Cnattingius et al , (female); the GOOD Study , (male); and Svensson et al , (male) were excluded from pooled gender analyses. One study  did not provide data on incidence of obesity, and was therefore excluded from the obesity analyses.
In total, 15 studies were included (combined population 163,753). Study descriptions and data are shown in table 1.
Data from 12 studies , ,,,–,,, (37,798 subjects; CS = 2995, VD = 34,803) were included in the random-effects meta-analysis which showed an unadjusted mean BMI difference of 0·44 kg·m−2 CI [0·17, 0·72], p = 0·002, I2 = 39% (Figure 2). The OR for incidence of overweight following CS in comparison to VD was 1·26 CI [1·16, 1·38], p<0·00001, I2 = 0% (Figure 3). A population of 37,622 (CS = 2975, VD = 34,647) from 11 studies , , , , –, , ,  was available to investigate the association between mode of delivery and obesity; the OR for CS in comparison to VD was 1·22 CI [1·05, 1·42], p = 0·01, I2 = 22% (Figure 4).
Forest Plot showing the pooled gender, unadjusted mean BMI difference in adult offspring by mode of delivery.
Forest Plot showing the pooled gender, unadjusted OR for incidence of overweight in adult offspring, by mode of delivery.
Men: Data from 13 studies , , –, , , , , ,  (40,229 subjects; CS = 3791, VD = 36,438) were included. The mean difference in BMI between CS and VD was 0·42 kg·m−2 CI [0·18, 0·67], p = 0·0008, I2 = 40% (Figure S2A). The OR for overweight was 1·21 CI [1·02, 1·43], p = 0·03, I2 = 56% (Figure S2B). Twelve studies , , –, , , , ,  (40,157 subjects; CS = 3776, VD = 36,378), were suitable to investigate obesity (1·33 CI [1·16, 1·53], p<0·0001, I2 = 8% (Figure S2C)
Women: Data from 12 studies , , , , , , –, , ,  (123,069 subjects; CS = 18,134, VD = 104,935) were included. The mean difference in BMI between CS and VD was 0·72 kg·m−2 CI [0·27, 1·18], p = 0·002, I2 = 74% (Figure S3A). The OR for overweight was 1·28 CI [1·12, 1·47], p = 0·0004, I2 = 44% (Figure S3B). Eleven studies , , , , , , , , , ,  (122,965 subjects; CS = 18,126, VD = 104,839) were suitable to investigate obesity (1·30 CI [1·05, 1·62], p = 0·02, I2 = 55% (Figure S3C).
Meta-regression showed the observed gender difference for BMI was not statistically significant (p = 0·25).
Emergency/in-labour-CS: Data from 4 studies , , ,  (17,943 subjects; in-labour-CS = 281, VD = 17,662) were suitable for inclusion. There were no significant differences in BMI, overweight and obesity comparing in-labour-CS to VD (mean BMI difference: 0·48 kg·m−2 CI [−0·08, 1·04], p = 0·09, I2 = 7% (Figure S4A); overweight OR: 1·21 CI [0·95, 1·53], p = 0·12, I2 = 0% (Figure S4B); obesity OR: 1·26 CI [0·78, 2·05], p = 0·35, I2 = 39% (Figure S4C). The population available to investigate the incidence of obesity was 17,776 (in-labour-CS = 270; VD = 17,506), from 3 studies , , .
Elective/pre-labour-CS: Data from the same 4 studies , , ,  (17,923 subjects; pre-labour-CS = 261, VD = 17,662) were included. There were no significant differences in BMI, overweight or obesity OR (mean BMI difference: 0·32 kg·m−2 CI [−0·21, 0·85], p = 0·24, I2 = 0% (Figure S5A); overweight OR 1·20 CI [0·93, 1·55], p = 0·15, I2 = 0% (Figure S5B); obesity OR: 1·13 CI [0·80, 1·59], p = 0·50, I2 = 0% (Figure S5C). The population for the evaluation of obesity was 17,758 (pre-labour-CS = 252; VD = 17,506) from 3 studies , , .
Subgroup analyses of CS against VD for all studies reporting type of CS showed similar effect-sizes to the overall analysis (mean BMI difference: 0·43 kg·m−2 [0·02, 0·85] (p = 0·04); overweight OR: 1·20 [1·01, 1.43] (p = 0·04); obesity OR: 1·21 [0·96; 1·54] (p = 0·11)). As there was no evidence of any difference in magnitude of effect when comparing type of CS (pre-labour-CS or in-labour-CS, compared to VD) on any outcome (BMI, overweight or obesity), a test comparing whether the effect varied between types of CS was not carried out.
Data from Cnattingius et al  (n = 103,941; not included in the sub-group analysis as the study only included women), showed significant mean BMI differences when comparing each type of CS to VD; in-labour-CS vs. VD: 1·40 kg·m−2 [1·28, 1·52] (p<0·00001), pre-labour-CS vs. VD: 1·00 kg·m−2 [0·89, 1·11] (p<0·00001). Interaction tests  show these differences in mean BMI difference between in-labour-CS and pre-labour-CS (compared to VD) to be statistically significant (p<0·001).
However, data from Svensson et al  (data on type of CS were only available for two years but were compared to the entire VD population; CS n = 533, VD n = 18,913; not included in the sub-group analysis as the study included only men), showed no significant mean BMI differences when comparing each type of CS to VD; in-labour-CS vs. VD: 0.30 kg·m−2 [−0.18, 0.78] p = 0.22, pre-labour-CS vs. VD: 0.20 kg·m−2 [−0.43,0.83] (p = 0.54).
Twenty-five percent of participants in Mi et al  and 40% of ACONF  were siblings but the statistical analysis did not reflect this. Furthermore, the implausible BMI values we noted in 1958 British Birth Cohort  brings into question the integrity of the dataset. To ensure that these potentially erroneous data did not bias the results, a sensitivity analysis was undertaken, excluding each study individually. Exclusion of these studies showed similar effect-sizes in all analyses (Table S1).
Study quality: Newcastle-Ottawa Scale scores (out of 7*) ranged from 3* to 7* (median = 4*; table 1). A sensitivity analysis of high quality studies (>4*) , , , ,  showed greater effect-sizes (mean BMI difference: 0·69 kg·m−2 [0·36, 1·02], p<0.0001; overweight OR: 1·33 [1·20, 1·47], p<0·00001; obesity OR: 1.27 [1.03, 1.57], p = 0.02).
Age of offspring
Mean offspring age at BMI measurement ranged from 18 to 69·6 years in the primary pooled gender analysis. Meta-regression showed a borderline significant decrease in mean difference in BMI with increasing mean offspring age, 0·023 kg·m−2 ([0·0008, 0·046], p = 0·06) less in mean BMI difference, per year increase in mean age (Figure S6).
Funnel plots and publication bias
A summary of all meta-analysis results is presented in table 2.
In this large systematic review and meta-analysis investigating the association between mode of delivery and adult BMI, overweight and obesity, we found an average increase in BMI of almost 0·5 kg·m−2 in subjects delivered by CS compared to VD, and an increased odds of overweight and obesity >20%; these findings are consistent across sexes. We found some indication that studies of younger populations showed greater effect-size.
Given that rate of CS has changed over time; driven partially by changing clinical practice and by the rise of the maternal choice CS, it is possible that the impact of CS on outcomes may be different dependent on the birth year of the cohort. Studies with a higher background CS rate, and studies where participants were born after 1975, have higher effect sizes and narrower confidence intervals (figure S10, S11). The narrower confidence intervals may be in part a reflection of the increased size of the CS groups. These figures demonstrate that inclusion of the older cohorts in our meta-analysis is likely to attenuate the effect sizes we report. This emphasises that the relationship between mode of delivery and later life outcomes is likely to be of increasing importance in future populations.
There are strengths and limitations to our systematic review and meta-analysis. A key strength is the large population of 142,702 subjects, from ten countries, spanning four continents; a large part of which have not been previously published in this form. Pre-registration of an a priori protocol prevented post hoc modifications to analyses, decreasing the risk of bias. Furthermore, heterogeneity was low in all primary analyses given all studies were observational. Prediction intervals were calculated to indicate the likely range of study effects in the presence of heterogeneity. We showed that while on average BMI was higher in the CS group, this may not occur in all settings as the prediction interval ranged from −0.27 to 1.15 kg·m−2. A similar finding was observed for obesity, but there was minimal heterogeneity in the analysis of overweight. All studies were of comparable high quality, limited only by low follow-up rates (mean follow-up rate across all included studies was 60%) and exclusion of studies with lower quality scores increased effect-sizes.
Despite these strengths, there were limitations. Funnel plot asymmetry suggested the possibility of reporting bias, but Egger's Test was statistically non-significant and as the outlying studies are in the opposite direction to the pooled results, any bias present probably attenuates rather than accentuates the findings. There was no evidence of a statistically significant gender difference in effect. Furthermore, gender-specific analyses showed higher levels of heterogeneity than the main results, possibly because the population size for each study is halved so the study estimates are less precise.
Collection of mode of delivery data in cohort studies was poor; these data were recorded in only 16 studies out of 33 identified (<15% of the total population of potential studies identified). Also, considerable aggregate data were unavailable for inclusion: 16 studies (a combined population >260,000 subjects) were identified in which relevant data had been collected, yet these were only available from 13, (142,280 subjects). A lack of patient level data prevented adjustment for confounders.
Findings from our meta-analysis are consistent with findings from other investigators. Shortly after completing our review, Li et al  reported 50% higher odds of obesity in adults born by CS compared to their VD counterparts from a systematic review and meta-analysis. In contrast to our findings: a greater effect size among higher quality studies, Li et al  found the association between CS and overweight/obesity no longer significant in a subgroup analysis limited to high quality studies (including 2 studies and 6,354 subjects). The small size of the Li et al subgroup analysis limits its findings, and we suggest that the apparently conflicting results of our subgroup analysis limited to high quality studies reflects the more inclusive nature of our review. Unlike Li et al , we were not limited by a small dataset and were therefore able to perform subgroup analyses, investigating the effects of gender on overall outcome, which they had initially set out to do. Furthermore, the availability of more data, in addition to contacting the authors for further information, we were able to present the risk of overweight and obesity separately, as well as specific BMI differences. Li et al  were however, able to present an adjusted pooled analysis, which due to a lack of patient level information we were unable to do. However, of note is that the adjusted estimate correlates closely with the unadjusted estimates we have shown through this study.
Goldani et al  reported the odds of obesity in adults born by CS to be 50% higher, and importantly, when they adjusted for confounders (see table 1), the effect of CS on offspring BMI was slightly increased. Barros et al  found no effect of CS on incidence of adult offspring obesity either before, or after, adjustment for a range of confounders (see table 1). This may be due to lack of power in the Barros study , as suggested by Li et al . One key difference between the two Brazilian studies is that Barros et al  were able to adjust the data for maternal pre-pregnancy height and weight unlike Goldani et al. This could account for the differences seen, but the unadjusted results from the Barros study still showed no significant difference in obesity between the two groups.
A key consideration is whether the associations we have identified between mode of delivery and offspring outcome are causal or reflect confounding. Plausible causal factors that might lead from CS to greater risk of obesity include differences in offspring microbiome as this differs between CS and VD neonates , leading to increased energy harvesting , and a lower rate of breastfeeding , in turn associated with greater risk of later-life overweight and obesity . Non-exposure to labour also results in persistence of fetal gene expression and altered metabolism . Nonetheless several factors associated with increased risk of CS are also associated with increased BMI in offspring, including high maternal BMI , gestational diabetes , and lower socioeconomic status , . Of these, maternal obesity is probably the most significant confounding factor in the relationship between CS and offspring BMI. This needs elucidation in datasets which can be properly controlled for maternal BMI.
To our best knowledge there have been no previous attempts to evaluate the effect of exposure to labour on later-life BMI, by examining outcomes in in-labour-CS and pre-labour-CS. When data were stratified by type of CS, we found no significant differences in adult BMI, overweight and obesity. However, these data were provided in only 5 studies, and the number of CS-delivered participants included in these subgroup analyses was <10% of the total number of CS deliveries in the main meta-analysis. Given the lack of power we do not feel that reliable conclusions can be drawn regarding the possibility of an impact of exposure to labour on study outcomes.
Our meta-analysis shows reduced association between CS and later-life BMI in older subjects. Exposure to post-natal obesogenic environmental factors increases with age, and may mask the association between CS and increased BMI in later life. However, as overweight and obesity track across time and are amplified in an obesogenic environment it seems unlikely that any impact of CS is truly attenuated with age. Hence we consider this is most likely due to the rising prevalence of obesity driving a larger effect-size in younger populations, although, longitudinal follow-up of these cohorts will be necessary to establish this with certainty.
In 2010 the WHO identified increased short-term adverse effects to mother and baby  following CS without medical indication. Controversially despite this evidence, and without considering possible long-term adverse outcomes, the highly influential UK NICE guidelines  were modified in 2011 to support offering CS to women who, after discussion with a mental health expert, feel that VD is an unacceptable option. Concern has been expressed that this guideline will further serve to fuel the already high and rapidly rising CS delivery rate worldwide. Associations between CS and increased later life risk of overweight and obesity are of significant relevance to population health. This requires that the possibility of a causal relationship be addressed as a matter of urgency, at the very least to provide the sound evidence required for women to make an informed decision regarding the advisability of delivery by CS in the absence of medical indication.
We thank all of the authors listed in table 1 who kindly supplied additional unpublished data for inclusion in this meta-analysis. We also thank the UK Data Archive and the Economic and Social Data Service for supplying data from the 1970 British Cohort Study and the 1958 National Child Development Study. These surveys are conducted by the Centre for Longitudinal Studies at the Institute for Education.
Conceived and designed the experiments: MJH SS CG NM. Performed the experiments: KD MJH SS CG. Analyzed the data: KD MJH SS CG. Wrote the paper: KD MJH SS CG NM.
- 1. National Obesity Observatory (2011) International comparisons of obesity prevalence revised April 2011.
- 2. The NHS Information Centre for Health and Social Care. Health survey for England – 2010: Respiratory health, 2011. Available: Www.ic.nhs.uk/pubs/hse10report. Accessed 2012 Aug 30.
- 3. Department of Health. Obesity. Available: http://www.dh.gov.uk/health/category/policy-areas/public-health/obesity-healthy-living/. Accessed 2012 Aug 30.
- 4. NHS Institute for Innovation and Improvement. Focus on: Caesarean section.
- 5. World Health Organisation (1985) Appropriate technology for birth. Lancet 2: 436–437.
- 6. Zhang J, Liu Y, Meikle S, Zheng J, Sun W, et al. (2008) Cesarean delivery on maternal request in southeast china. Obstet Gynecol 111: 1077–1082.
- 7. Victora CG, Aquino EM, do Carmo Leal M, Monteiro CA, et al. (2011) Maternal and child health in Brazil: Progress and challenges. Lancet 377: 1863–1876.
- 8. Bragg F, Cromwell DA, Edozien LC, Gurol-Urganci I, Mahmood TA, et al. (2010) Variation in rates of caesarean section among English NHS trusts after accounting for maternal and clinical risk: Cross sectional study. BMJ 341: c5065.
- 9. Hyde MJ, Mostyn A, Modi N, Kemp PR (2012) The health implications of birth by caesarean section. Biol Rev Camb Philos Soc 87: 229–243.
- 10. Annibale DJ, Hulsey TC, Wagner CL, Southgate WM (1995) Comparative neonatal morbidity of abdominal and vaginal deliveries after uncomplicated pregnancies. Arch Pediatr Adolesc Med 149: 862–867.
- 11. Villar J, Carroli G, Zavaleta N, Donner A, Wojdyla D, et al. (2007) Maternal and neonatal individual risks and benefits associated with caesarean delivery: Multicentre prospective study. BMJ 335: 1025.
- 12. Utz RL (2008). can prenatal care prevent childhood obesity? in policy perspectives, vol. 4. university of utah, utah.
- 13. Goldani HA, Bettiol H, Barbieri MA, Silva AA, Agranonik M, et al. (2011) Cesarean delivery is associated with an increased risk of obesity in adulthood in a Brazilian birth cohort study. Am J Clin Nutr 93: 1344–1347.
- 14. Barros FC, Matijasevich A, Hallal PC, Horta BL, Barros AJ, et al. (2012) Cesarean section and risk of obesity in childhood, adolescence, and early adulthood: Evidence from 3 Brazilian birth cohorts. Am J Clin Nutr 95: 465–470.
- 15. Hyde M, Modi N, Gale C, Darmasseelane K, Shalini S. Mode of delivery and offspring Body Mass Index, overweight and obesity in adult life: a systematic review and meta-analysis. Available: www.crd.york.ac.uk/PROSPERO/display_record.asp?ID=CRD42011001851.
- 16. Moher D, Liberati A, Tetzlaff J, Altman DG (2009) PRISMA Group (2009) Preferred reporting items for systematic reviews and meta-analyses: The PRISMA statement. BMJ 339: b2535.
- 17. National Institute for Health and Clinical Excellence (2006) [obesity]. [CG43]. London: National institute for health and clinical excellence.
- 18. Wells GA, Shea B, O'Connell D, Petersen J, Welch V, et al. The Newcastle-Ottawa scale (NOS) for assessing the quality of nonrandomized studies in meta-analyses. Department of epidemiology and community medicine, University of Ottawa, Canada.
- 19. Higgins JP, Thompson SG (2002) Quantifying heterogeneity in a meta-analysis. Stat Med 21: 1539–1558.
- 20. Deeks JJ, Altman DG, Bradburn MJ (2001) Statistical methods for examining heterogeneity and combining results from several studies in meta-analysis. In: Egger M, Smith GD, Adltman DG, editors. Systematic Review in Health Care: Meta-analysis in Context: BMJ Publishing Group. pp. 285–312.
- 21. Hardy RJ, Thompson SG (1998) Detecting and describing heterogeneity in meta-analysis. Stat Med 17: 841–856.
- 22. Egger M, Davey Smith G, Schneider M, Minder C (1997) Bias in meta-analysis detected by a simple, graphical test. BMJ 315: 629–634.
- 23. Higgins JP, Thompson SG, Spiegelhalter DJ (2009) A re-evaluation of random-effects meta-analysis. J R Stat Soc Ser A Stat Soc 172: 137–159.
- 24. Wu CS, Nohr EA, Bech BH, Vestergaard M, Catov JM, et al. (2009) Health of children born to mothers who had preeclampsia: A population-based cohort study. Am J Obstet Gynecol 201: 269.e1–269.e10.
- 25. Tuvemo T, Cnattingius S, Jonsson B (1999) Prediction of male adult stature using anthropometric data at birth: A nationwide population-based study. Pediatr Res 46: 491–495.
- 26. Fall CH, Dennison E, Cooper C, Pringle J, Kellingray SD, et al. (2002) Does birth weight predict adult serum cortisol concentrations? twenty-four-hour profiles in the united kingdom 1920-1930 Hertfordshire birth cohort. J Clin Endocrinol Metab 87: 2001–2007.
- 27. Kahn HS, Narayan KM, Williamson DF, Valdez R (2000) Relation of birth weight to lean and fat thigh tissue in young men. Int J Obes Relat Metab Disord 24: 667–672.
- 28. Parker L, Lamont DW, Unwin N, Pearce MS, Bennett SM, et al. (2003) A lifecourse study of risk for hyperinsulinaemia, dyslipidaemia and obesity (the central metabolic syndrome) at age 49-51 years. Diabet Med 20: 406–415.
- 29. Barker DJ, Bull AR, Osmond C, Simmonds SJ (1990) Fetal and placental size and risk of hypertension in adult life. BMJ 301: 259–262.
- 30. Ravelli AC, van Der Meulen JH, Osmond C, Barker DJ, Bleker OP (1999) Obesity at the age of 50 y in men and women exposed to famine prenatally. Am J Clin Nutr 70: 811–816.
- 31. Nilsson PM, Ostergren PO, Nyberg P, Soderstrom M, Allebeck P (1997) Low birth weight is associated with elevated systolic blood pressure in adolescence: A prospective study of a birth cohort of 149378 swedish boys. J Hypertens 15: 1627–1631.
- 32. Pouta A, Hartikainen AL, Sovio U, Gissler M, Laitinen J, et al. (2004) Manifestations of metabolic syndrome after hypertensive pregnancy. Hypertension 43: 825–831.
- 33. Harlap S, Davies AM, Deutsch L, Calderon-Margalit R, Manor O, et al. (2007) The Jerusalem perinatal study cohort, 1964-2005: Methods and a review of the main results. Paediatr Perinat Epidemiol 21: 256–273.
- 34. Lithell HO, McKeigue PM, Berglund L, Mohsen R, Lithell UB, et al. (1996) Relation of size at birth to non-insulin dependent diabetes and insulin concentrations in men aged 50-60 years. BMJ 312: 406–410.
- 35. Sorensen HT, Sabroe S, Rothman KJ, Gillman M, Fischer P, et al. (1997) Relation between weight and length at birth and body mass index in young adulthood: Cohort study. BMJ 315: 1137.
- 36. Robinson S, Walton RJ, Clark PM, Barker DJ, Hales CN, et al. (1992) The relation of fetal growth to plasma glucose in young men. Diabetologia 35: 444–446.
- 37. Valdez R, Athens MA, Thompson GH, Bradshaw BS, Stern MP (1994) Birthweight and adult health outcomes in a biethnic population in the USA. Diabetologia 37: 624–631.
- 38. Bager P, Melbye M, Rostgaard K, Benn CS, Westergaard T (2003) Mode of delivery and risk of allergic rhinitis and asthma. J Allergy Clin Immunol 111: 51–56.
- 39. Leon DA, Lawlor DA, Clark H, Macintyre S (2006) Cohort profile: The aberdeen children of the 1950s study. Int J Epidemiol 35: 549–552.
- 40. Eriksson JG, Kajantie E, Thornburg KL, Osmond C, Barker DJ (2011) Mother's body size and placental size predict coronary heart disease in men. Eur Heart J 32: 2297–2303.
- 41. Rudang R, Mellstrom D, Clark E, Ohlsson C, Lorentzon M (2012) Advancing maternal age is associated with lower bone mineral density in young adult male offspring. Osteoporos Int 23: 475–482.
- 42. Mi J, Law C, Zhang KL, Osmond C, Stein C, et al. (2000) Effects of infant birthweight and maternal body mass index in pregnancy on components of the insulin resistance syndrome in china. Ann Intern Med 132: 253–260.
- 43. Vonk JM, Boezen HM, Postma DS, Schouten JP, van Aalderen WM, et al. (2004) Perinatal risk factors for bronchial hyperresponsiveness and atopy after a follow-up of 20 years. J Allergy Clin Immunol 114: 270–276.
- 44. Kajantie E, Eriksson J, Barker DJ, Forsen T, Osmond C, et al. (2003) Birthsize, gestational age and adrenal function in adult life: Studies of dexamethasone suppression and ACTH1-24 stimulation. Eur J Endocrinol 149: 569–575.
- 45. Stein CE, Fall CH, Kumaran K, Osmond C, Cox V, et al. (1996) Fetal growth and coronary heart disease in south india. Lancet 348: 1269–1273.
- 46. Kajantie E, Strang-Karlsson S, Hovi P, Raikkonen K, Pesonen AK, et al.. (2010) Adults born at very low birth weight exercise less than their peers born at term. J Pediatr 157: : 610–6, 616.e1.
- 47. Cnattingius S, Villamor E, Lagerros YT, Wikstrom AK, Granath F (2011) High birth weight and obesity-a vicious circle across generations. Int J Obes (Lond).
- 48. Ros HS, Lichtenstein P, Ekbom A, Cnattingius S (2001) Tall or short? twenty years after preeclampsia exposure in utero: Comparisons of final height, body mass index, waist-to-hip ratio, and age at menarche among women, exposed and unexposed to preeclampsia during fetal life. Pediatr Res 49: 763–769.
- 49. Lagerstrom M, Bremme K, Eneroth P, Janson CG (1994) Long-term development for girls and boys at age 16-18 as related to birth weight and gestational age. Int J Psychophysiol 17: 175–180.
- 50. Rooney BL, Mathiason MA, Schauberger CW (2011) Predictors of obesity in childhood, adolescence, and adulthood in a birth cohort. Matern Child Health J 15: 1166–1175.
- 51. Svensson E, Hyde MJ, Modi N, Ehrenstein V (2013) Caesarean section and body mass index among Danish adult men. Obesity (Silver Spring).
- 52. Braddon FE, Rodgers B, Wadsworth ME, Davies JM (1986) Onset of obesity in a 36 year birth cohort study. Br Med J (Clin Res Ed) 293: 299–303.
- 53. Parsons TJ, Power C, Manor O (2001) Fetal and early life growth and body mass index from birth to early adulthood in 1958 British cohort: Longitudinal study. BMJ 323: 1331–1335.
- 54. University of London. Institute of Education. Centre for longitudinal studies, national child development study: Childhood data, sweeps 0-3, 1958-1974 [computer file]. 2nd edition. national birthday trust fund, national children's bureau, [original data producer(s)]. Colchester, Essex: UK data archive [distributor], august 2008. SN: 5565, http://dx.doi.org/10.5255/UKDA-SN-5565-1.
- 55. University of London. Institute of Education. Centre for longitudinal studies, national child development study: Sweep 5, 1991 [computer file]. 2nd edition. city university. social statistics research unit, [original data producer(s)]. Colchester, Essex: UK data archive [distributor], august 2008. SN: 5567.
- 56. University of London. Institute of Education. Centre for longitudinal studies, national child development study: Sweep 8, 2008-2009: First deposit [computer file]. 2nd edition. Colchester, Essex: UK data archive [distributor], march 2010. SN: 6137.
- 57. White B, Nicholls D, Christie D, Cole TJ, Viner RM (2012) Childhood psychological function and obesity risk across the lifecourse: Findings from the 1970 British cohort study. Int J Obes (Lond) 36: 511–516.
- 58. Chamberlain R, Chamberlain G. 1970 British cohort study: Birth and 22-month subsample, 1970-1972 [computer file]. 2nd edition. Colchester, Essex: UK data archive [distributor], august 2008. SN: 2666, http://dx.doi.org/10.5255/UKDA-SN-2666-1.
- 59. University of London. Institute of Education. Centre for longitudinal studies, 1970 British cohort study: Thirty-four-year follow-up, 2004-2005 [computer file]. 2nd edition. Colchester, Essex: UK data archive [distributor], august 2008. SN: 5585, http://dx.doi.org/10.5255/UKDA-SN-5585-1.
- 60. Barker DJ, Osmond C, Golding J, Kuh D, Wadsworth ME (1989) Growth in utero, blood pressure in childhood and adult life, and mortality from cardiovascular disease. BMJ 298: 564–567.
- 61. Miller FJ, Billewicz WZ, Thomson AM (1972) Growth from birth to adult life of 442 newcastle upon tyne children. Br J Prev Soc Med 26: 224–230.
- 62. Jaquet D, Gaboriau A, Czernichow P, Levy-Marchal C (2000) Insulin resistance early in adulthood in subjects born with intrauterine growth retardation. J Clin Endocrinol Metab 85: 1401–1406.
- 63. Altman DG, Bland JM (2003) Interaction revisited: The difference between two estimates. BMJ 326: 219.
- 64. Li HT, Zhou YB, Liu JM (2012) The impact of cesarean section on offspring overweight and obesity: A systematic review and meta-analysis. Int J Obes (Lond).
- 65. Li HT, Zhou YB, Liu JM (2012) Cesarean section might moderately increase offspring obesity risk. Am J Clin Nutr 96: 215–216.
- 66. Biasucci G, Benenati B, Morelli L, Bessi E, Boehm G (2008) Cesarean delivery may affect the early biodiversity of intestinal bacteria. J Nutr 138: 1796S–1800S.
- 67. Turnbaugh PJ, Ley RE, Mahowald MA, Magrini V, Mardis ER, et al. (2006) An obesity-associated gut microbiome with increased capacity for energy harvest. Nature 444: 1027–1031.
- 68. Prior E, Santhakumaran S, Gale C, Philipps LH, Modi N, et al.. (2012) Breastfeeding after cesarean delivery: A systematic review and meta-analysis of world literature. Am J Clin Nutr.
- 69. Harder T, Bergmann R, Kallischnigg G, Plagemann A (2005) Duration of breastfeeding and risk of overweight: A meta-analysis. Am J Epidemiol 162: 397–403.
- 70. Chu SY, Kim SY, Schmid CH, Dietz PM, Callaghan WM, et al. (2007) Maternal obesity and risk of cesarean delivery: A meta-analysis. Obes Rev 8: 385–394.
- 71. Philipps LH, Santhakumaran S, Gale C, Prior E, Logan KM, et al. (2011) The diabetic pregnancy and offspring BMI in childhood: A systematic review and meta-analysis. Diabetologia 54: 1957–1966.
- 72. McLaren L (2007) Socioeconomic status and obesity. Epidemiol Rev 29: 29–48.
- 73. Gould JB, Davey B, Stafford RS (1989) Socioeconomic differences in rates of cesarean section. N Engl J Med 321: 233–239.
- 74. Souza JP, Gulmezoglu A, Lumbiganon P, Laopaiboon M, Carroli G, et al. (2010) Caesarean section without medical indications is associated with an increased risk of adverse short-term maternal outcomes: The 2004-2008 WHO global survey on maternal and perinatal health. BMC Med 8: 71.
- 75. National Institute for Health and Clinical Excellence (2011) [caesarean section]. [CG132]. London: National institute for health and clinical excellence.