Skip to main content
International Journal of Epidemiology logoLink to International Journal of Epidemiology
. 2017 Jan 23;46(3):839–849. doi: 10.1093/ije/dyw346

Change in birth outcomes among infants born to Latina mothers after a major immigration raid

Nicole L Novak 1,*, Arline T Geronimus 2,3, Aresha M Martinez-Cardoso 2
PMCID: PMC5837605  PMID: 28115577

Abstract

Background: Growing evidence indicates that immigration policy and enforcement adversely affect the well-being of Latino immigrants, but fewer studies examine ‘spillover effects’ on USA-born Latinos. Immigration enforcement is often diffuse, covert and difficult to measure. By contrast, the federal immigration raid in Postville, Iowa, in 2008 was, at the time, the largest single-site federal immigration raid in US history.

Methods: We employed a quasi-experimental design, examining ethnicity-specific patterns in birth outcomes before and after the Postville raid. We analysed Iowa birth-certificate data to compare risk of term and preterm low birthweight (LBW), by ethnicity and nativity, in the 37 weeks following the raid to the same 37-week period the previous year (= 52 344). We model risk of adverse birth outcomes using modified Poisson regression and model distribution of birthweight using quantile regression.

Results: Infants born to Latina mothers had a 24% greater risk of LBW after the raid when compared with the same period 1 year earlier [risk ratio (95% confidence interval) = 1.24 (0.98, 1.57)]. No such change was observed among infants born to non-Latina White mothers. Increased risk of LBW was observed for USA-born and immigrant Latina mothers. The association between raid timing and LBW was stronger among term than preterm births. Changes in birthweight after the raid primarily reflected decreased birthweight below the 5th percentile of the distribution, not a shift in mean birthweight.

Conclusions: Our findings highlight the implications of racialized stressors not only for the health of Latino immigrants, but also for USA-born co-ethnics.

Keywords: immigration enforcement, birth outcomes, stress, Latinos/Hispanics, nativity


Key Messages

  • We compare risk of adverse birth outcomes before and after a major federal immigration raid in Postville, Iowa.

  • Whereas there was no change in risk of low birthweight for infants born to White mothers in Iowa, infants born to Latina mothers in Iowa had a 24% higher risk of low birthweight in the period following the Postville raid.

  • Analyses including gestational age reveal an elevation in risk of moderate-preterm birth (PTB) after the raid among Latina mothers, rather than an increase in very-PTB.

  • These findings are consistent with theories linking immigration enforcement to the health of Latino immigrants and their USA-born co-ethnics.

Introduction

Investigators theorize that unintended consequences of social policies affecting disadvantaged groups contribute to entrenched US health disparities.1–5 A growing literature examines effects of US immigration policy on immigrants (particularly Latino immigrants),5 documenting links between immigration policy and health care utilization,6–9 Medicaid participation10,11 or food insecurity.12 A smaller, but growing number of studies examine links between immigration enforcement and psychosocial well-being,13,14 self-rated health15 and enforcement-related distress.15–17

Many existing studies of immigration policy/enforcement and health focus on immigrant (or specifically undocumented-immigrant) samples18 or examine Latinos regardless of nativity.6,7,15 Whereas some studies have documented effects of immigration policy and enforcement on USA-born children of immigrants,9,11,19 far fewer examine implications specifically for co-ethnic USA-born adults.8,12,16 Although USA-born Latinos are not subject to immigration deportation, many are embedded in communities targeted by immigration enforcement20,21 and may experience discrimination, ‘othering’20 or chronic identity-related vigilance22 in response to racialized exclusion.5,23–26

Measuring causal relationships between immigration policy/enforcement and health outcomes has proved challenging: policy changes usually occur after an extended deliberation period that makes exposure classification difficult, and enforcement practices are often diffuse and covert.10,21 In contrast, the 2008 Immigration and Customs Enforcement (ICE) raid on a meat-processing plant in Postville, Iowa, was the largest single-site raid yet seen in the USA, and occurred without warning, allowing a clear before-and-after comparison.

We compare risk of adverse birth outcomes among Latina and non-Latina White mothers in the state of Iowa before and after the Postville raid. Birth outcomes, and particularly low birthweight (LBW), are well suited as health outcomes in this study because birth-certificate data are publicly available and collected for all births regardless of the mother’s immigration status, and birthweight has little measurement error. Previous studies have documented increased LBW risk after population-level stressors such as terrorist attacks or natural disasters27–31 (although some studies report null or mixed findings).32,33

Economic and demographic commonalities across Latino population clusters in Iowa (many, like Postville, centre on meat processing) and social and affective ties between foreign-born and USA-born Latinos lead us to hypothesize effects for Latinos across the entire state. We hypothesize that, among Iowa births, the association between LBW and birth after the raid will be modified by mother’s ethnicity, such that foreign-born and USA-born Latina mothers will have higher LBW rates after the raid, whereas non-Latina White mothers will have no change in LBW. We anticipate that this effect modification will be independent of potential socio-economic confounders and traditional risk factors for LBW.

Exposure: the Postville raid

The ICE raid on a meat-processing plant in Postville, Iowa, on 12 May 2008 was implemented without advance warning to local or state officials. ICE deployed 900 agents using military tactics, including armed officers and a UH-60 Black Hawk helicopter, to arrest 389 employees, 98% of whom were Latino.34 Agents used presumed race/ethnicity to identify suspected undocumented immigrants, allegedly handcuffing all employees assumed to be Latino until their immigration status was verified.35

Male arrestees were detained at the National Cattle Congress in Waterloo, Iowa (80 miles from Postville), whereas women were detained in county jails. Mothers of small children were allowed to return to Postville with ankle monitors but, barred from working, survived on charitable aid.34,36 Detainees were chained together and arraigned in groups of 10 for felony charges of aggravated identity theft (knowingly working under a false Social Security Number). A plea bargain led nearly all to plead guilty, although few were technically guilty of the crime, and 297 arrestees were deported after serving a 5-month prison sentence.34

The raid separated hundreds of families, most often from their primary breadwinner. Fear of follow-up home raids kept many Postville families from staying in their own homes, choosing instead to sleep in church pews or leave town altogether.36 News of the raid immediately spread throughout the state. La Prensa, a Spanish-language newspaper in western Iowa, published eyewitness testimony of arrestees detained at a cattle fairground, cuffed and chained together from the waist to the ankles.37

Methods

We obtained birth-certificate data for all births in Iowa from 2006 to 2010 (= 209 389). We classified infants as ‘exposed’ to the post-raid environment if they were born in the 37 weeks following the Postville raid (12 May 2008–26 January 2009) and ‘unexposed’ if they were born in same period one year earlier (12 May 2007–26 January 2008). We chose 37 weeks because it was the minimum length of a normal gestation.

The primary outcome variable, LBW, was defined as birthweight <2500 g. We used self-reported race and Hispanic ethnicity to categorize mothers as Latina or non-Latina White, creating a ‘Latina’ category by restricting to mothers in any Hispanic subgroup except Hispanic/Spaniard. Latina mothers were predominantly of Mexican descent (81%), although 11% were of Central American origin and 8% were of other Hispanic origin. We used self-reported birthplace to categorize mothers as USA- or foreign-born. Immigration status is not collected in birth-certificate data. We included data on maternal age (<20, 20–25, 26–30, 31–35, 36–40, 41+ years), education (<8th grade, 9th–11th grade, high-school diploma/equivalent, some college/Associate’s degree, college diploma), marital status (married/unmarried at conception) and parity (first live birth/second or higher). We also divided maternal education into tertiles within strata of ethnicity/nativity. We included data on prenatal maternal smoking (no smoking, <10, 10–19, 20+ cigarettes/day) and prenatal care utilization (Kessner index for adequate, intermediate and inadequate prenatal care).38

We used a data-cleaning algorithm to create a gestational age (GA) variable, which we categorized into preterm birth (PTB) and categories of GA. We took this step to address previously reported data-quality issues for GA estimation in vulnerable populations, including immigrant, Latina or low-English-proficient mothers and mothers with late prenatal care initiation.39–42 The algorithm used a LMP-based estimate of GA wherever possible, and the clinical estimate when a LMP-based estimate was unavailable or implausible for the infant’s birthweight; for more information, see Basso and Wilcox.43 PTB was defined as GA < 37 weeks. We further categorized GA as very-preterm (<32 weeks), moderate-preterm (32–36 weeks), early-term (37–38 weeks) and full-term (≥39 weeks).44,45

We used the cleaned GA variable to estimate the stage of gestation at the time of the raid (or the comparison date), classifying infants as not yet conceived, or in the first, second or third trimester on the date of interest.

We restricted our analysis to singletons born in the 37 weeks following the raid or the same period one year earlier (= 57 850), although we include data from the same period 2 years earlier (= 26 531) for description. We excluded 4659 infants born to mothers who were not Latina or non-Latina White, and those missing data on birthweight (= 20), GA (= 115), maternal nativity (Latina mothers only, = 11), age (= 2), education (= 332), marital status (= 6), parity (= 256) and prenatal smoking (= 105). Excluded infants (= 847) were more likely to be LBW, both among Latina and non-Latina White mothers. The final sample included 52 344 infants, 25 979 born in the 37 weeks following the Postville raid and 26 365 born during the same 37-week period 1 year earlier.

Statistical methods

We used modified Poisson regression46 to estimate risk ratios (RRs) comparing risk of LBW among infants born after Postville to those in the comparison period, and used Knol and VanderWeele’s recommended methods for presenting analyses of effect modification.47 This involved presenting: (i) RRs for each stratum of maternal ethnicity and birth timing with a single reference category; (ii) RRs for being born after the raid, stratified on maternal ethnicity; and (iii) measures of effect modification on the additive scale (relative excess risk due to interaction: RERI) and multiplicative scale (ratio of RRs).48,49 We estimated a second set of models with Latina mothers further stratified on nativity.

To confirm that findings were not confounded by changes in the population of mothers, we re-estimated all models, first with adjustments for maternal risk factors for LBW (age, education, marital status and parity). We further adjusted for measured health behaviours that could have mediated changes in LBW after Postville: maternal smoking and prenatal care utilization.

We conducted additional analyses to better understand observed changes in LBW. We stratified our initial models on PTB to evaluate whether shifts in LBW were operating primarily on term or preterm births. We used conditional quantile regression50,51 to analyse the distribution of birthweight among Latinas by exposure period. Quantile regression models the association of the exposure with the full range of the birthweight distribution, not merely above or below the set cut-off of 2500 g for LBW.51,52 Quantiles were specified to evaluate changes in birthweights lower than the 2500-g cut-off as well as changes throughout the full distribution of birthweight: the 2nd, 5th, 10th, 25th, 50th, 75th, 90th, 95th and 98th percentiles were considered. We estimated the association of birth post-raid with the distribution of birthweight, bootstrapping results 1000 times to estimate standard errors and confidence intervals.

We also examined changes in categories of GA (very-preterm, moderate-preterm, early-term, full-term) before and after the raid, among Latina mothers, using multinomial logistic regression with robust standard errors.

To examine differences in LBW risk according to stage of pregnancy at the time of the raid, we repeated initial analyses with the sample further stratified by stage of gestation at the time of the raid.30,53,54 We estimated RRs for LBW after the raid compared with before the raid, by ethnicity and gestational category. To determine whether changes in risk of LBW varied by social position within strata of ethnicity/nativity, we also estimated LBW models stratified on within-group tertiles of education. Analyses were conducted with STATA 13.

Results

Traditional risk factors for LBW and PTB varied by maternal ethnicity and nativity; however, within ethnicity/nativity groups, the distribution of maternal socio-demographic characteristics remained consistent before and after the raid, as did mean birthweight (Table 1). Prior to the raid, Latina and White mothers had similar prevalence of LBW (4.7% for both) and PTB (7.5% for both), which is consistent with other reports of ethnicity-specific birth outcomes in Iowa in this period.55,56

Table 1.

Descriptive statistics by mother’s ethnicity/nativity, during the 37 weeks following the Postville raid (12 May 2008–26 January 2009) and during the same time period 1 year earlier (12 May 2007–26 January 2008) (= 52 344)

White
Foreign-born Latina
USA-born Latina
Time period Before raid (= 23 878) After raid (= 23 379) Before raid (= 1689) After raid (= 1746) Before raid (= 798) After raid (= 854)
Mean % Mean % Mean % Mean % Mean % Mean %
Infant sex
Male 51.3 51.5 50.4 50.2 50.4 48.7
Female 48.7 48.5 49.6 49.7 49.6 51.3
Mother’s age (years)
<20 7.7 7.8 9.9 9.3 27.3 27.3
20–25 32.5 31.1 33.3 33.1 38.5 39.0
26–30 33.2 34.1 27.5 27.7 22.1 20.3
31–35 18.6 18.9 19.7 21.0 8.9 9.4
36–40 6.9 6.9 8.1 7.9 2.9 3.2
41+ 1.1 1.1 1.5 1.0 0.4 0.9
Education
8th grade or less 1.3 1.2 34.2 33.7 2.6 2.9
Some high-school education 8.2 8.2 35.5 36.2 33.6 32.4
High-school diploma/equivalent 21.4 20.4 18.1 18.4 31.1 30.8
Some college 38.5 38.8 8.2 7.8 26.2 26.2
College degree+ 30.7 31.4 4.1 3.9 6.5 7.6
Maternal marital status
Mother unmarried 31.3 31.7 44.9 47.0 64.5 56.8
Mother married 68.7 68.3 55.1 53.0 35.5 43.2
Parity
0 previous 40.0 39.8 28.4 27.8 41.1 40.4
1 or more previous 60.0 60.2 71.5 72.2 59.9 59.6
Prenatal care (Kessner Index)
Inadequate 2.2 2.2 5.0 4.9 4.8 3.9
Intermediate 7.7 7.7 19.2 17.5 13.4 15.2
Adequate 90.1 90.1 75.7 77.6 81.8 80.9
Smoking in pregnancy
No smoking 80.0 80.7 98.7 99.1 82.0 87.2
<10 cigarettes/day 10.3 10.2 1.1 0.9 12.7 9.1
10–19 cigarettes/day 7.4 6.9 0.2 0.1 3.6 3.0
20+ cigarettes/day 2.4 2.2 0.1 1.8 0.6
Low birthweight 4.7 4.4 4.5 5.6 5.3 6.4
Mean birthweight (g) 3401 3407 3349 3339 3336 3315
Preterm birth 7.5 7.5 7.8 8.0 7.5 8.9

Figure 1 displays temporal trends in LBW, by ethnicity and nativity, including the two time periods in the study sample and also extending an additional year earlier (12 May 2006–26 January 2007). Among White mothers, rates of LBW declined slightly (as has been the trend nationwide since 2006).57 Among Latina mothers, rates of LBW were stable in 2006–07, but rose among USA- and foreign-born Latina mothers after the raid.

Figure 1.

Figure 1

Descriptive graph: rates of low birthweight (LBW) in the 37 weeks following the Postville raid compared with the same time period 1 and 2 years earlier.

As displayed in Table 2, the RRs [95% confidence intervals (CIs)] comparing risk of LBW after the raid to before the raid were 1.24 (0.98–1.57) among Latina mothers and 0.95 (0.87–1.03) among White mothers. The measure of effect modification on the additive scale, the RERI, was 0.30 (95% CI 0.03–0.57) and the measure of effect modification on the multiplicative scale, the ratio of RRs, was 1.31 (1.02–1.68). RRs and effect modification measures were robust to adjustment for potential confounders and mediators (Supplementary Tables 1 and 2, available as Supplementary data at IJE online).

Table 2.

Modified Poisson regression results for risk of LBW by time period of birth (before/after Postville raid) and mother’s ethnicity (White/Latina) (= 52 344)

Before raid
After raid
RR (95% CI); P for after raid vs before within strata of ethnicity
N LBW/non RR (95% CI); P N LBW/non RR (95% CI); P
White mother 1112/22 766 1.0 (Reference) 1029/22 350 0.95 (0.87, 1.03); = 0.18 0.95 (0.87, 1.03); = 0.18
Latina mother 118/2369 1.02 (0.84, 1.23); =0.84 153/2447 1.31 (1.02, 1.68); =  0.03 1.24 (0.98, 1.57); = 0.07

Measure of effect modification on additive scale: RERI (95% CI) = 0.30 (0.03, 0.57); = 0.03. Measure of effect modification on multiplicative scale: ratio of RRs (95% CI): 1.31 (1.02, 1.68); = 0.03. RRs and measures of effect modification are unadjusted.

Table 3 displays the same models with Latina mothers further stratified by nativity. Although confidence intervals widen because of the smaller sample in each group, the RRs (95% CIs) for LBW after the raid among foreign-born (1.25, 0.93–1.67) and USA-born Latina mothers (1.22, 0.83–1.81) were similar in magnitude to the RR from the pooled model, as were the effect modification measures. Adjustment for potential confounders or mediators did not affect these findings (Supplementary Tables 3 and 4, available as Supplementary data at IJE online).

Table 3.

Modified Poisson regression results for risk of LBW by time period of birth (before/after Postville raid) and mother’s ethnicity/nativity (White/foreign-born Latina/USA-born Latina) (= 52 344)

Before raid
After raid
RR (95% CI); P for after raid vs before within strata of ethnicity
N BW/non RR (95% CI); P N LBW/non RR (95% CI); P
White mother 1112/22 766 1.0 (Reference) 1029/22 350 0.95 (0.87, 1.03); = 0.18 0.95 (0.87, 1.03); = 0.18
Foreign-born Latina mother 76/1613 0.97 (0.77, 1.21); = 0.77 98/1648 1.32 (0.97, 1.79); = 0.07 1.25 (0.93, 1.67); = 0.14
USA-born Latina mother 42/756 1.13 (0.84, 1.53); = 0.42 55/799 1.29 (0.87, 1.93); = 0.20 1.22 (0.83, 1.81); = 0.31

Measure of effect modification on additive scale: RERI (95% CI) = 0.29 (–0.03, 0.62); = 0.07 (for Foreign-born Latinas), 0.31 (–0.18, 0.80); = 0.22 (for USA-born Latinas). Measure of effect modification on multiplicative scale: ratio of RRs (95% CI) = 1.32 (0.97, 1.79); = 0.07 (for Foreign-born Latinas), 1.29 (0.87, 1.93); P = 0.20 (for USA-born Latinas). RRs and measures of effect modification are unadjusted.

In models stratified by term/preterm births, LBW was more strongly associated with birth post-raid among term infants born to Latina mothers (RR, 95% CI = 1.49, 0.95–2.33) than among preterm infants (1.08, 0.88–1.33) (results not shown).

Multinomial logistic regression comparing categories of GA, by ethnicity, before and after Postville, reveals an elevation in risk of moderate-PTB after the raid among Latina mothers (relative risk ratio, 95% CI = 1.11, 0.89–1.38), but no change in risk of very-PTB (0.81, 0.46–1.41) (Table 4).

Table 4.

Multinomial logistic regression results, categories of gestational age at birth in 37 weeks following the Postville raid compared with same period 1 year earlier, by maternal ethnicity (= 52 344)

Gestational age at birth White (= 47 907) RR (95% CI); P Latina (= 5149) RR (95% CI); P
Full-term (reference) (39+ weeks) 1.00 1.00
Early-term (37–38 weeks) 0.91 (0.87, 0.95); <0.01 0.92 (0.81, 1.04); =0.20
Moderate-preterm (32–36 weeks) 0.97 (0.90, 1.04); =0.39 1.11 (0.89, 1.38); =0.34
Very-preterm (<32 weeks) 0.96 (0.79, 1.17); =0.70 0.81 (0.46, 1.41); =0.45

Quantile regression on the distribution of birthweight indicated that, among Latina mothers, birth post-raid was associated with reduced birthweight only at the left tail of the birthweight distribution, where infants below the 5th percentile of birthweight (corresponding to 2518 g before the raid) were 88 g lighter after the raid (95% CI –168g to –8g). Birth post-raid was not associated with differences in birthweight among infants below the 2nd percentile of birthweight, which corresponded to 2084 g before the raid (6 g heavier, 95% CI –224g to –236g) or at any other point in the birthweight distribution.

In models examining risk of LBW among Latina mothers stratified by stage of gestation at the time of the raid, we found the strongest association between LBW and birth post-raid among mothers in the first trimester at the time of the raid (RR, 95% CI = 1.39, 0.97–1.98) (Table 5). In LBW models stratified by within-group tertiles of education, we observed the strongest association between LBW and birth post-raid in the lower two tertiles of education for both immigrant and USA-born Latina mothers (Table 6).

Table 5.

Modified Poisson regression results for risk of LBW by time period of birth (before/after Postville raid) and mother’s ethnicity (White/Latina), stratified by stage of gestation at time of Postville raid (= 52 344)

White mothers Latina mothers Measures of effect modification
Stage of gestation at time of Postville raid RR (95% CI); P RR (95% CI); P Ratio of RRs (95% CI); P RERI (95% CI); P
Not yet conceived (= 359) 1.12 (0.93, 1.35); =0.24 1.03 (0.65, 1.63); =0.89 0.92 (0.56, 1.52); =0.75 –0.08 (–0.70, 0.54); = 0.81
First trimester (= 14 302) 0.89 (0.78, 1.02); =0.10 1.39 (0.97, 1.98); =0.07 1.55 (1.06, 2.27); =0.02 0.49 (0.07, 0.92); = 0.02
Second trimester (= 23 355) 0.98 (0.87, 1.11); =0.75 1.12 (0.79, 1.59); =0.54 1.14 (0.79, 1.65); =0.49 0.14 (–0.26, 0.55); =0.49
Third trimester (= 14 687) 1.00 (0.81, 1.23); =0.98 1.12 (0.58, 2.13); =0.74 1.12 (0.58, 2.16); =0.74 0.12 (–0.58, 0.81); = 0.74

Table 6.

Modified Poisson regression results for risk of LBW by time period of birth (before/after Postville raid) and mother’s ethnicity and nativity, stratified by approximate within-group tertiles of education (= 52 344)

Non-Latina White mothers
Foreign-born Latina mothers
USA-born Latina mothers
(= 47 257)
(= 3435)
(= 1652)
Within-group tertiles of education (n) RR for birth after Postville raid Within-group tertiles of education (n) RR for birth after Postville raid Within-group tertiles of education (n) RR for birth after Postville raid
High-school diploma (= 14 334) 0.95 (0.83, 1.08) Less than 8th grade (= 1165) 1.42 (0.90, 2.25) Less than high school (= 591) 1.18 (0.68, 2.06)
Associate’s degree or some college (= 18 261) 0.98 (0.86, 1.12) Some high school (= 1232) 1.40 (0.84, 2.35) High-school diploma (= 511) 1.48 (0.78, 2.83)
College diploma or higher (= 14 662) 0.91 (0.76, 1.09) High school or greater (= 1038) 0.89 (0.51, 1.57) Some college or greater (= 550) 0.90 (0.32, 2.54)

Discussion

We used the Postville raid, a large-scale immigration raid implemented without warning, as a natural experiment to investigate the effects of immigration enforcement on birth outcomes among Latina mothers in a Mid-western state. We found that rates of LBW were steady among White and Latina mothers in the 2 years preceding the raid, but that rates of LBW rose only among Latina mothers after the raid. The association between birth post-raid and LBW was modified by maternal ethnicity on both the additive (RERI > 0) and multiplicative scales (ratio of RRs > 1). This association was evident among both foreign-born and USA-born Latina mothers and persisted after adjustment for maternal risk factors, maternal smoking and prenatal care utilization.

We found that the increases in LBW were greatest among term births, but that there was also a higher prevalence of moderate-preterm (not very-preterm) infants after the raid. Previous studies of psychosocial stressors and birth outcomes have found that LBW increased both through increased PTB30,53 and through intrauterine growth restriction58,59; it appears that both mechanisms operated in Iowa, which is plausible given the diversity of economic and psychosocial pathways by which the raid may have affected Latina mothers.

Comparing births after Postville to births in the same period 1 year earlier accounted for seasonality in birth outcomes and avoided the ‘mechanical correlation’ between pregnancy duration and risk of exposure to stressful events—a methodological pitfall in studies using the time period immediately preceding an event as the comparison period.33

Our examination of births in the entire state of Iowa makes this a conservative analysis as one might hypothesize stronger effects in or near Postville compared with Latino communities farther away. Previous studies have examined dose–response relationships based on geographic distance from a natural disaster or attack28,33 but, for privacy reasons, the Iowa Department of Public Health does not release microdata with date of birth and geographic information. However, we do not have reason to believe that stressors resulting from Postville raid would emanate by geographic distance in as dramatic a way as a geographically confined natural disaster or attack. Many Latino communities in Iowa are economically similar to Postville, and communication networks between communities make it plausible that Latinos across the state would feel connected to an enforcement event targeted at a single workplace. Lauderdale’s finding of increased LBW among Arabic-named mothers in California after the attacks of 11 September 2001 that occurred across the country in New York City lends plausibility to the view that social identity threats can affect co-ethnics at remote distances.

LBW risk increased most among Latina mothers with lower educational attainment (less than high school for the foreign-born and less than college for the USA-born). This could be because low-educated mothers were more vulnerable to the economic and psychosocial fallout of the raid or had fewer coping resources. Reports from throughout Iowa after the Postville raid include evidence of individuals and families preparing for the possibility of further immigration enforcement,37,60–62 avoiding public space,60,63 restricting spending,63,64 losing income or economic security due to changing employment practices62,65–68 and experiencing increased discrimination, stereotype threat or racialized exclusion as public discourse frequently conflated Latino/Hispanic phenotype with undocumented status.35,65 These reports align with findings from a recent quasi-experimental study in Michigan: after a local immigration raid led to several arrests and deportations, Latinos were more likely to report that they feared the consequences of deportation, and that their immigration status impeded social relationships.15 In the wake of the Postville raid, similar restrictions in social support and increases in day-to-day fear may have coalesced to increase psychosocial stress and reduce coping resources among Latino immigrants and USA-born co-ethnics. Following the raid, Latino Iowans likened the experience to a flood or earthquake, reflecting the profound impact of this stressor on their lives and on their health.69,70

Quantile regression indicated that the higher risk of LBW among Latina mothers after Postville resulted from decreased birthweight at the left tail of the distribution, not a shift in mean birthweight. This is similar to Lauderdale’s findings for ethnicity-specific change in birthweight after 9/11.71 Lower birthweights at the left tail of the birthweight distribution are more likely to be associated with infant mortality than a leftward shift of the entire distribution.71,72

Post-raid increases in LBW risk were greatest for Latina mothers in the first trimester of gestation at the time of the raid. Several other studies have also found stronger effects among first-trimester exposures,27,29,30,73 but others have not.31,33,53,54 Our finding in Iowa could suggest that early-gestation infants were more vulnerable, or it may be that those infants were simply exposed to the post-raid environment for a larger proportion of gestation.

Several complex immune, inflammatory and endocrine pathways are proposed to link psychosocial stressors and birthweight. One hypothesis is that maternal psychosocial stress disrupts the balance between maternal glucocorticoid levels and 11 beta-hydroxysteroid dehydrogenase type 2 (HSD2), an enzyme that metabolizes cortisol into inactive cortisone.74,75 Placental HSD2 typically up-regulates in tandem with serum glucocorticoid levels during gestation, protecting the fetus from 80–90% of circulating maternal glucocorticoids.76 However, psychosocial stress and disruption of maternal emotional support have been linked to both higher prenatal glucocorticoid concentrations and lower placental HSD2,75,77–79 both of which are linked to LBW.76,80–84 The psychosocial, economic, communal and identity-based stressors activated by the Postville raid may have interfered with Latina mothers’ neuroendocrine balance and coping resources, leaving infants vulnerable to a dysregulated endocrine environment.

Limitations

If healthy pregnant Latinas left Iowa after Postville, increased LBW among Latinas might reflect selection effects. However, analysing Census data,85 we found no evidence that the raid was associated with a change in the size of Iowa’s Latino population, overall or among women of reproductive age. And, as noted, we found no difference in demographic characteristics among Latina mothers before or after the raid.

There is random year-to-year variation in LBW prevalence, especially in small populations, which raises concerns that the observed increase in LBW among Latina mothers was a chance finding. We do not have access to birth microdata pre-2006, but we used publicly available data56 to calculate crude LBW prevalences among singleton births to non-Hispanic White and Hispanic mothers during May–January for the 5 years preceding and following the raid. LBW prevalence among infants born to Hispanic mothers is higher from May 2008 to January 2009 than in any other May–January period from 2003 to 2013 (Supplementary Figure 1, available as Supplementary data at IJE online).

Birth-certificate data for birthweight, maternal ethnicity and maternal birthplace have high validity relative to medical records.86–89 However, data on GA are of lower quality,86 particularly for Latina and non-English-proficient mothers,39,41 which affects our classification of PTB and stage of gestation at the time of the raid. We used a data-cleaning algorithm to mitigate data-quality issues, but this entails several assumptions90 and, whereas it is unlikely that remaining misclassification of GA differs by raid timing, even non-differential misclassification may have biased findings for PTB and stage of gestation towards the null. Birth-certificate data for our hypothesized mediators, prenatal smoking and prenatal care are also of lower quality,86–88 which reduces our ability to observe mediation by changed health behaviours.

Conclusions

Our findings are consistent with studies observing changes in adverse birth outcomes after a major population-level stressor28,30,53,71 and contribute to literature on racialized stressors and ethnicity-specific birth outcomes.32,71 We extend the literature on immigration policy/enforcement and health by specifically examining a physical outcome and by examining both immigrant and USA-born Latinos.

The Postville raid was an extreme example of diffuse and pervasive racialized economic and psychosocial stressors that Latinos face throughout the USA. The scale and temporality of this event created conditions that lend insight into the pervasive effects of these stressors, which are often difficult to measure. Exclusive immigration policies and their militarized enforcement exacerbate the racialized exclusion of Latinos in the USA, which may contribute to a cumulative health burden for immigrant and USA-born Latinos alike.

Supplementary Data

Supplementary data are available at IJE online.

Funding

This work was supported in by the National Institutes of Health (grant numbers T32 AG000221, T32 HD007339), the Rackham Graduate School at the University of Michigan (grant number U028717–185539) and the Center for Advanced Study in the Behavioral Sciences at Stanford. The funding sources had no involvement in study design; in the collection, analysis and interpretation of data; in the drafting of the manuscript; or in the decision to submit it for publication. The study protocol was approved by the Institutional Review Board of the Iowa Department of Public Health (Research Agreement 2718) and determined to be ‘not regulated’ by the Health Sciences and Behavioral Sciences Institutional Review Board of the University of Michigan (HUM00074761).

Conflict of interest: The authors have no conflicts of interest to declare.

Supplementary Material

Supplementary Figure

References

  • 1. Richman LS, Hatzenbuehler ML.. A multilevel analysis of stigma and health: implications for research and policy. Policy Insights Behav Brain Sci 2014;1:213–21. [Google Scholar]
  • 2. Geronimus AT, Pearson JA, Linnenbringer E. et al. Race-ethnicity, poverty, urban stressors, and telomere length in a Detroit community-based sample. J Health Soc Behav 2015;56:199–224. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 3. Pearson JA. Can’t buy me whiteness. Du Bois Rev Soc Sci Res Race 2008;5:27–47. [Google Scholar]
  • 4. Keene DE, Padilla MB.. Race, class and the stigma of place: moving to ‘opportunity’ in Eastern Iowa. Health Place 2010;16:1216–23. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 5. Viruell-Fuentes EA, Miranda PY, Abdulrahim S.. More than culture: structural racism, intersectionality theory, and immigrant health. Soc Sci Med 2012;75:2099–106. [DOI] [PubMed] [Google Scholar]
  • 6. Beniflah JD, Little WK, Simon HK. et al. Effects of immigration enforcement legislation on Hispanic pediatric patient visits to the pediatric emergency department. Clin Pediatr (Phila) 2013;52(12):1122–126. [DOI] [PubMed] [Google Scholar]
  • 7. Rhodes SD, Mann L, Siman FM. et al. The impact of local immigration enforcement policies on the health of immigrant Hispanics/Latinos in the United States. Am J Public Health 2015;105:329–37. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 8. Toomey RB, Umana-Taylor AJ, Williams DR. et al. Impact of Arizona’s SB 1070 immigration law on utilization of health care and public assistance among Mexican-origin adolescent mothers and their mother figures. Am J Public Health 2014;104(Suppl 1):S28–34. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 9. White K, Yeager VA, Menachemi N. et al. Impact of Alabama’s immigration law on access to health care among Latina immigrants and children: implications for national reform. Am J Public Health 2014;104:397–405. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 10. Vargas ED. Immigration enforcement and mixed-status families: the effects of risk of deportation on Medicaid use. Child Youth Serv Rev 2015;57:83–9. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 11. Watson T. Inside the refrigerator: immigration enforcement and chilling effects in Medicaid participation. Am Econ J Econ Policy 2014;6:313–38. [Google Scholar]
  • 12. Potochnick S, Chen J-H, Perreira K.. Local-level immigration enforcement and food insecurity risk among Hispanic immigrant families with children: national-level evidence. J Immigr Minor Health 2016; doi:10.1007/s10903-016-0464-5. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 13. Hacker K, Chu J, Leung C. et al. The impact of immigration and customs enforcement on immigrant health: perceptions of immigrants in Everett, Massachusetts, USA. Soc Sci Med 2011;73:586–94. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 14. Hacker K, Chu J, Arsenault L. et al. Provider’s perspectives on the impact of Immigration and Customs Enforcement (ICE) activity on immigrant health. J Health Care Poor Underserved 2012;23:651. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 15. Lopez WD, Kruger DJ, Delva J. et al. Health implications of an immigration raid: findings from a Latino community in the midwestern United States. J Immigr Minor Health 2016;doi:10.1007/s10903-016-0390-6. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 16. Quiroga SS, Medina DM, Glick J.. In the belly of the beast: effects of anti-immigration policy on Latino community members. Am Behav Sci 2014;58:1723–42. [Google Scholar]
  • 17. Sabo S, Shaw S, Ingram M. et al. Everyday violence, structural racism and mistreatment at the US-Mexico border. Soc Sci Med. 2014;109:66–74. [DOI] [PubMed] [Google Scholar]
  • 18. Martinez O, Wu E, Sandfort T. et al. Evaluating the impact of immigration policies on health status among undocumented immigrants: a systematic review. J Immigr Minor Health 2013;17:947–70. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 19. Dreby J. U.S. immigration policy and family separation: the consequences for children’s well-being. Soc Sci Med 2015;132:245–51. [DOI] [PubMed] [Google Scholar]
  • 20. Viruell-Fuentes EA. Beyond acculturation: immigration, discrimination, and health research among Mexicans in the United States. Soc Sci Med 2007;65:1524–35. [DOI] [PubMed] [Google Scholar]
  • 21. Maldonado MM. Latino incorporation and racialized border politics in the heartland: interior enforcement and policeability in an English-only state. Am Behav Sci 2014;58:1927–45. [Google Scholar]
  • 22. Geronimus AT, James SA, Destin M. et al. Jedi public health: co-creating an identity-safe culture to promote health equity. SSM—Popul Health 2016;2:105–16. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 23. Cobas JA, Duany J, Feagin JR.. How the United States Racializes Latinos: White Hegemony and Its Consequences. Routledge, 2009. [Google Scholar]
  • 24. Golash-Boza T. Dropping the hyphen? Becoming Latino (a)-American through racialized assimilation. Soc Forces 2006;85:27–55. [Google Scholar]
  • 25. Frank R, Akresh IR, Lu B.. Latino immigrants and the U.S. racial order: how and where do they fit in? Am Sociol Rev 2010;75:378–401. [Google Scholar]
  • 26. Arellano-Morales L, Roesch SC. et al. Prevalence and correlates of perceived ethnic discrimination in the Hispanic Community Health Study/Study of Latinos Sociocultural Ancillary Study. J Lat Psychol 2015;3:160–76. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 27. Mansour H, Rees DI.. Armed conflict and birth weight: evidence from the al-Aqsa Intifada. J Dev Econ 2012;99:190–9. [Google Scholar]
  • 28. Eskenazi B, Marks AR, Catalano R. et al. Low birthweight in New York City and upstate New York following the events of September 11th. Hum Reprod 2007;22:3013–20. [DOI] [PubMed] [Google Scholar]
  • 29. Camacho A. Stress and birth weight: evidence from terrorist attacks. Am Econ Rev 2008;98(2):511–15. [PubMed] [Google Scholar]
  • 30. Torche F. The effect of maternal stress on birth outcomes: exploiting a natural experiment. Demography 2011;48:1473–91. [DOI] [PubMed] [Google Scholar]
  • 31. Simeonova E. Out of sight, out of mind? Natural disasters and pregnancy outcomes in the USA. CESifo Econ Stud 2011;57:403–31. [Google Scholar]
  • 32. El-Sayed A, Hadley C, Galea S.. Birth outcomes among Arab Americans in Michigan before and after the terrorist attacks of September 11, 2001. Ethn Dis 2008;18:348–56. [PubMed] [Google Scholar]
  • 33. Currie J, Rossin-Slater M.. Weathering the storm: hurricanes and birth outcomes. J Health Econ 2013;32:487–503. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 34. Rigg RR. The Postville raid: a postmortem. Rutgers Race Rev 2011;12:271. [Google Scholar]
  • 35. Krogstad JM. In Postville, shock but no surprise. Waterloo-Cedar Falls Courier, 13 May 2008. (cited 21 February 2015). http://wcfcourier.com/news/metro/inpostvilleshockbutnosurprise/article_205edba8a0e159bea16b13ceae6628d6.html.
  • 36. Camayd-Freixas E. Interpreting after the largest ICE raid in US history: a personal account. New York Times, 2008. (cited 1 December 2012). http://graphics8.nytimes.com/images/2008/07/14/opinion/14ed-camayd.pdf.
  • 37. Lopez L. No somos animales. La Prensa, 16 May 2008 (cited 21 February 2015). http://www.laprensaiowa.com/5-16/local.html. [Google Scholar]
  • 38. Kessner D, Singer J, Kalk C, Shlesinger E.. Infant Death: An Analysis by Maternal Risk and Health Care. Institute of Medicine and National Academy of Sciences, 1973. [Google Scholar]
  • 39. Dietz PM, England LJ, Callaghan WM. et al. A comparison of LMP-based and ultrasound-based estimates of gestational age using linked California livebirth and prenatal screening records. Paediatr Perinat Epidemiol 2007;21 (Suppl 2):62–71. [DOI] [PubMed] [Google Scholar]
  • 40. Bengiamin MI, Capitman JA, Ruwe MB.. Disparities in initiation and adherence to prenatal care: impact of insurance, race-ethnicity and nativity. Matern Child Health J 2010;14:618–24. [DOI] [PubMed] [Google Scholar]
  • 41. Wingate MS, Alexander GR, Buekens P. et al. Comparison of gestational age classifications: date of last menstrual period vs. clinical estimate. Ann Epidemiol 2007;17:425–30. [DOI] [PubMed] [Google Scholar]
  • 42. Reichman NE, Schwartz-Soicher O.. Accuracy of birth certificate data by risk factors and outcomes: analysis of data from New Jersey. Am J Obstet Gynecol 2007;197:32.e1–32.e8. [DOI] [PubMed] [Google Scholar]
  • 43. Basso O, Wilcox A.. Mortality risk among preterm babies: immaturity versus underlying pathology. Epidemiology 2010;21:521–7. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 44. Engle WA. A recommendation for the definition of ‘late preterm’ (near-term) and the birth weight–gestational age classification system. Optim Care Outcomes Late Preterm–Termin Part 1 2006;30:2–7. [DOI] [PubMed] [Google Scholar]
  • 45. Gynecologists AC of O and ACOG Committee Opinion No 579: definition of term pregnancy. Obstet Gynecol 2013;122:1139–40. [DOI] [PubMed] [Google Scholar]
  • 46. Cummings P. Methods for estimating adjusted risk ratios. Stata J 2009;9:175. [Google Scholar]
  • 47. Knol MJ, VanderWeele TJ.. Recommendations for presenting analyses of effect modification and interaction. Int J Epidemiol 2012;41:514–20. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 48. Altman DG, Bland JM.. Interaction revisited: the difference between two estimates. BMJ 2003;326:219. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 49. Richardson DB, Kaufman JS.. Estimation of the relative excess risk due to interaction and associated confidence bounds. Am J Epidemiol 2009;169:756–60. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 50. Chernozhukov V, Fernández-Val I.. Inference for extremal conditional quantile models, with an application to market and birthweight risks. Rev Econ Stud 2011;78:559–89. [Google Scholar]
  • 51. Abrevaya J, Dahl CM.. The effects of birth inputs on birthweight: evidence from quantile estimation on panel data. J Bus Econ Stat 2008;26:379–97. [Google Scholar]
  • 52. Liu SY, Kawachi I, Glymour MM.. Education and inequalities in risk scores for coronary heart disease and body mass index: evidence for a population strategy. Epidemiology 2012;23:657–64. [DOI] [PubMed] [Google Scholar]
  • 53. Carlson K. Fear itself: The effects of distressing economic news on birth outcomes. J Health Econ 2015;41:117–32. [DOI] [PubMed] [Google Scholar]
  • 54. Class QA, Lichtenstein P, Langstrom N. et al. Timing of prenatal maternal exposure to severe life events and adverse pregnancy outcomes: a population study of 2.6 million pregnancies. Psychosom Med 2011;73:234–41. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 55. France J, Johnson D, Jungling J.. Vital Statistics of Iowa. Center for Health Statistics, Iowa Department of Public Health, 2006. http://idph.iowa.gov/Portals/1/Files/HealthStatistics/vital_stats_2006.pdf. [Google Scholar]
  • 56. Natality public-use data 2003–2006, on CDC Wonder Online Database, March 2009. United States Department of Health and Human Services (US DHHS), Centers for Disease Control and Prevention (CDC), National Center for Health Statistics (NCHS), Division of Vital Statistics (cited 7 July 2016. http://wonder.cdc.gov/natality-v2006.html.
  • 57. Martin JA, Hamilton BE, Osterman MJ. et al. Births: final data for 2013. Natl Vital Stat Rep Cent Dis Control Prev Natl Cent Health Stat Natl Vital Stat Syst 2015;64:1–65. [PubMed] [Google Scholar]
  • 58. Margerison-Zilko CE, Catalano R, Hubbard A. et al. Maternal exposure to unexpected economic contraction and birth weight for gestational age. Epidemiology 2011;22:855–8. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 59. Eiríksdóttir VH, Ásgeirsdóttir TL, Bjarnadóttir RI. et al. Low birth weight, small for gestational age and preterm births before and after the economic collapse in Iceland: a population based cohort study. PLoS ONE 2013;8:e80499. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 60. Jacobs J, Perkins J. Immigration raid: workers take care, take cover. Des Moines Register, 12 May 2008. (cited 21 February 2015). http://archive.desmoinesregister.com/article/20080513/NEWS/805130402/.
  • 61. Christensen E. Area Hispanics scurry to get paperwork in line. Waterloo-Cedar Falls Courier, 12 May 2008. (cited 21 February 2015). http://wcfcourier.com/news/top_story/areahispanicsscurrytogetpaperworkinline/article_805fc83ff238527e9aae638fcedbd414.html.
  • 62. Toopes C. Diversity group discusses immigration rumors. Ottumwa Courier, 29 May 2008. (cited 21 February 2015). http://www.ottumwacourier.com/news/local_news/diversitygroupdiscussesimmigrationrumors/article_21109416a790557ba7a40b749c549399.html.
  • 63.90 miles away, Postville raid’s impact is still being felt. Mason City Globe Gazette, 25 May 2008. (cited 21 February 2015). http://globegazette.com/news/local/miles-away-postville-raid-s-impact-is-still-being-felt/article_ed576161–6c5c-5543–8d9b-ac0857480bd3.html.
  • 64. Burns D. Postville raid raises worries in Denison Latino community, activist says. Iowa Independent, 23 May 2008. (cited 21 February 2015). http://iowapoliticalalert.blogspot.com/2008/05/postvilleraidraisesworriesin.html.
  • 65. Saul T. Eastern Iowa Hispanic community fears more raids. Quad-City Times, 22 May 2008. (cited 21 February 2015). http://siouxcityjournal.com/news/eastern-iowa-hispanic-community-fears-more-raids/article_20a51fb3-24e0-55be-b65b-98b82089b5ae.html.
  • 66. Larsen D. SL. does not foresee immigration raid, but concerns continue. Storm Lake Pilot Tribune, 28 August 2008. (cited 21 February 2015). http://www.stormlakepilottribune.com/story/1518320.html.
  • 67. Jackson HC. Town wonders if it’s next to face immigration raid. USA Today, 26 August 2008. (cited 21 February 2015). http://usatoday30.usatoday.com/news/nation/200808261720516720_x.htm.
  • 68. Jones M. Postville, Iowa, is up for grabs. New York Times Magazine, July 15, 2012. [Google Scholar]
  • 69. Gibbs VG, Hernández L.. Shattered Dreams: The Story of a Historic ICE Raid in the Words of the Detainees. Floricanto Press, 2014. [Google Scholar]
  • 70. Brosnan G. The Postville immigration raid: like a great flood. Rev Harv Rev Lat Am 2011;Fall 2010/Winter 2011:70–1. [Google Scholar]
  • 71. Lauderdale DS. Birth outcomes for Arabic-named women in California before and after September 11. Demography 2006;43:185–201. [DOI] [PubMed] [Google Scholar]
  • 72. Wilcox AJ. On the importance—and the unimportance—of birthweight. Int J Epidemiol 2001;30:1233–41. [DOI] [PubMed] [Google Scholar]
  • 73. Zhu P, Tao F, Hao J. et al. Prenatal life events stress: implications for preterm birth and infant birthweight. Am J Obstet Gynecol 2010;203:34.e1–34.e8. [DOI] [PubMed] [Google Scholar]
  • 74. Reynolds RM. Glucocorticoid excess and the developmental origins of disease: two decades of testing the hypothesis—2012 Curt Richter Award Winner. Psychoneuroendocrinology 2013;38:1–11. [DOI] [PubMed] [Google Scholar]
  • 75. O’Donnell KJ, Bugge Jensen A, Freeman L. et al. Maternal prenatal anxiety and downregulation of placental 11β-HSD2. Psychoneuroendocrinology 2012;37:818–26. [DOI] [PubMed] [Google Scholar]
  • 76. Benediktsson R, Calder AA, Edwards CR. et al. Placental 11 beta-hydroxysteroid dehydrogenase: a key regulator of fetal glucocorticoid exposure. Clin Endocrinol 1997;46:161–6. [DOI] [PubMed] [Google Scholar]
  • 77. Reynolds RM, Pesonen A-K, O’Reilly JR. et al. Maternal depressive symptoms throughout pregnancy are associated with increased placental glucocorticoid sensitivity. Psychol Med 2015;45:2023–30. [DOI] [PubMed] [Google Scholar]
  • 78. La Marca-Ghaemmaghami P, La Marca R, Dainese SM. et al. The association between perceived emotional support, maternal mood, salivary cortisol, salivary cortisone, and the ratio between the two compounds in response to acute stress in second trimester pregnant women. J Psychosom Res 2013;75:314–20. [DOI] [PubMed] [Google Scholar]
  • 79. Graignic-Philippe R, Dayan J, Chokron S. et al. Effects of prenatal stress on fetal and child development: a critical literature review. Neurosci Biobehav Rev 2014;43:137–62. [DOI] [PubMed] [Google Scholar]
  • 80. Bolten MI, Wurmser H, Buske-Kirschbaum A. et al. Cortisol levels in pregnancy as a psychobiological predictor for birth weight. Arch Womens Ment Health 2011;14:33–41. [DOI] [PubMed] [Google Scholar]
  • 81. Guardino CM, Schetter CD, Saxbe DE. et al. Diurnal salivary cortisol patterns prior to pregnancy predict infant birth weight. Health Psychol 2016;35:625–33. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 82. Baibazarova E, van de Beek C, Cohen-Kettenis PT. et al. Influence of prenatal maternal stress, maternal plasma cortisol and cortisol in the amniotic fluid on birth outcomes and child temperament at 3 months. Psychoneuroendocrinology 2013;38:907–15. [DOI] [PubMed] [Google Scholar]
  • 83. McTernan CL, Draper N, Nicholson H. et al. Reduced placental 11beta-hydroxysteroid dehydrogenase type 2 mRNA levels in human pregnancies complicated by intrauterine growth restriction: an analysis of possible mechanisms. J Clin Endocrinol Metab 2001;86:4979–83. [DOI] [PubMed] [Google Scholar]
  • 84. Cottrell EC, Seckl JR.. Prenatal stress, glucocorticoids and the programming of adult disease. Front Behav Neurosci 2009;3:19. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 85. Ruggles S, Genadek K, Goeken R. et al. Integrated Public Use Microdata Series: Version 6.0 [machine-readable database]. University of Minnesota, 2015.
  • 86. DiGiuseppe DL, Aron DC, Ranbom L. et al. Reliability of birth certificate data: a multi-hospital comparison to medical records information. Matern Child Health J 2002;6:169–79. [DOI] [PubMed] [Google Scholar]
  • 87. Northam S, Knapp TR.. The reliability and validity of birth certificates. J Obstet Gynecol Neonatal Nurs 2006;35:3–12. [DOI] [PubMed] [Google Scholar]
  • 88. Buescher PA, Taylor KP, Davis MH. et al. The quality of the new birth certificate data: a validation study in North Carolina. Am J Public Health 1993;83:1163–5. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 89. Baumeister L, Marchi K, Pearl M. et al. The validity of information on ‘race’ and ‘Hispanic ethnicity’ in California birth certificate data. Health Serv Res 2000;35:869–83. [PMC free article] [PubMed] [Google Scholar]
  • 90. Parker JD, Schoendorf KC.. Implications of cleaning gestational age data. Paediatr Perinat Epidemiol 2002;16:181–7. [DOI] [PubMed] [Google Scholar]

Associated Data

This section collects any data citations, data availability statements, or supplementary materials included in this article.

Supplementary Materials

Supplementary Figure

Articles from International Journal of Epidemiology are provided here courtesy of Oxford University Press

RESOURCES