Reassessment of the risk of birth defects due to Zika virus in Guadeloupe, 2016

Abstract

Background information The ZIKA-DFA-FE cohort study (an acronym for “Zika in the French Territories in the Americas in Pregnant Women”), which has been described elsewhere,[12] used four different recruitment methods in an attempt to observe women whose pregnancies overlapped with the 2016 ZIKV epidemic period in the French Territories in the Americas (Guadeloupe, Martinique, French Guyana): 1) pregnant women with symptoms consistent with ZIKV infection, 2) pregnant women for whom a fetal abnormality was detected during routine fetal ultrasound examinations, 3) pregnant women who experienced fetal demise, and 4) pregnant women who delivered at participating hospitals during or up to nine months following the ZIKV epidemic period. Exactly as within the prospective cohort study, infant clinical data such as gestational age, length, weight, and head circumference, APGAR scores (1, 5 and 10 minutes of life) were collected on the day of birth, and a standardized clinical examination was carried out in the first four days of life. Study participants For the cross-sectional study, we selected women from the fourth recruitment method of the ZIKA-DFA-FE study who gave birth to a live neonate during or up to 9 months following the 2016 ZIKV epidemic period (in Guadeloupe, the epidemic lasted from April 4th to September 19th 2016), and who had a confirmed negative IgG serology test for ZIKV from blood taken at the time of delivery as well as no other positive or indeterminate ZIKV test during pregnancy. The odds ratio (OR) for the association between abnormalities in live born infants and Zika virus exposure during pregnancy was estimated through a multiple logistic regression model that included maternal age, occupational category, and ethnicity.

Introduction

Since the first evidence surfaced that linked Zika virus (ZIKV) to fetal microcephaly and other brain abnormalities,[1,2] key research priorities have been to define the range of defects associated with ZIKV infection during pregnancy, as well as to establish the risk of a fetus or infant being affected following ZIKV infection during pregnancy. A handful of case-series and case-control studies have now been summarized to establish a preliminary definition of Zika congenital syndrome (ZCS), which includes a range of ocular abnormalities and neurological defects, such as microcephaly, structural brain abnormalities, consequences of central nervous system dysfunction, swallowing disorders, irritability, seizures, neurodevelopmental issues, and others.[3–9] In terms of the overall risk of abnormalities following maternal ZIKV infection during pregnancy, this has been estimated as 46% (95%CI: 37–56) in a prospective cohort study from Brazil using a broader definition for ZIKV-associated outcomes, 5% (95%CI: 4–6) in a registry-based study in the United States of America, and 7% (95%CI: 5–10) and 13% (95%CI: 9–18) through two separate prospective cohort studies in the French Territories in the Americas.[10–13]

For the purpose of determining those birth defects that can actually be linked to ZIKV in an exposed population, an estimation of the baseline level of birth defects in an appropriate ZIKV non-infected control group is necessary. There has been minimal use of comparative control groups within prospective studies on this topic.[10,14,15] In Brazil, a prospectively followed control group demonstrated that total adverse outcomes were significantly fewer in women without evidence of ZIKV: 11% (95%CI 5–22) versus 46% (95%CI: 37–56); however, for some specific outcome categories, such as fetal demise and infants with microcephaly, there was no difference.[10] In Guadeloupe, in the absence of a prospective cohort of pregnant women without ZIKV infection, we recruited, at delivery, women and their live born infants who were known to have not been infected with ZIKV. We compared the proportion of congenital abnormalities in this ZIKV-negative group with that observed among a subset of live born infants (ie. all of those from Guadeloupe) from our prospective cohort of women in the French Territories in the Americas who developed symptomatic RT-PCR confirmed ZIKV infection at any time during pregnancy.[12]

Methods

Ethics statement

The ZIKA-DFA-FE study is registered with ClinicalTrials.gov (NCT02916732) and received ethics approval by the Comité de Protection des Personnes Sud-Ouest et Outremer III (CEBH2016/03), in compliance with the Declaration of Helsinki. All women provided written informed consent to have their, and their infants’, data included in this study.

Background information

The ZIKA-DFA-FE cohort study (an acronym for “Zika in the French Territories in the Americas in Pregnant Women”), which has been described elsewhere,[12] used four different recruitment methods in an attempt to observe women whose pregnancies overlapped with the 2016 ZIKV epidemic period in the French Territories in the Americas (Guadeloupe, Martinique, French Guyana): 1) pregnant women with symptoms consistent with ZIKV infection, 2) pregnant women for whom a fetal abnormality was detected during routine fetal ultrasound examinations, 3) pregnant women who experienced fetal demise, and 4) pregnant women who delivered at participating hospitals during or up to nine months following the ZIKV epidemic period. A prospective cohort of women infected with ZIKV during pregnancy was derived from the first recruitment method,[12] and a cross-sectional study of women and their live born infants not infected with ZIKV during pregnancy was derived from the fourth recruitment method, which will be described below.

Data collection

At the time of hospital admission for labor, each eligible woman was informed of the study and invited to participate; oral consent was obtained before delivery and written informed consent was obtained before delivery whenever possible or within 24 hours after delivery otherwise. A questionnaire exploring socio-demographic characteristics, such as age, ethnicity, education, profession, and lifestyle factors, was administered. Clinical information, including the number of previous pregnancies, history of adverse pregnancy outcomes, medical history, clinical symptoms consistent with ZIKV infection, and any other clinically significant medical event during pregnancy, was also collected. Exactly as within the prospective cohort study, infant clinical data such as gestational age, length, weight, and head circumference, APGAR scores (1, 5 and 10 minutes of life) were collected on the day of birth, and a standardized clinical examination was carried out in the first four days of life. The medical files of participants were reviewed to collect data on clinical and ultrasound examinations that were performed during the pregnancy.

Laboratory testing

All participating women had blood sampled on the day of delivery, from which sera were frozen and stored. These were tested for the presence of anti-ZIKV IgG antibodies, using the Euroimmun ZIKV IgG immunoassay (Euroimmun, Medizinische Labordiagnostika AG, Lübeck, Germany). The results of any other ZIKV tests (serological or molecular) or TORCH testing that had been performed on biological samples collected during the pregnancy were also recorded.

Study participants

For the cross-sectional study, we selected women from the fourth recruitment method of the ZIKA-DFA-FE study who gave birth to a live neonate during or up to 9 months following the 2016 ZIKV epidemic period (in Guadeloupe, the epidemic lasted from April 4th to September 19th 2016), and who had a confirmed negative IgG serology test for ZIKV from blood taken at the time of delivery as well as no other positive or indeterminate ZIKV test during pregnancy.

Anthropometric abnormalities and other birth defects in infants were classified according to the same case definitions as used in the prospective, ZIKV-exposed cohort study.[12] Microcephaly was defined as moderate when head circumference was between– 2 SD and– 3 SD and severe when head circumference was less than– 3 SD, based on the INTERGROWTH-21st standards (http://intergrowth21.ndog.ox.ac.uk/) for gestational age and sex. Moderate microcephaly was further defined as proportionate or disproportionate depending on whether the neonate was small for gestational age (ie. birth weight less than -1.28 SD).[10,12,16] Clinical examination records and ultrasound files of participants were reviewed for evidence of birth defects that are considered to be potentially associated with ZIKV infection according to the current definition of ZCS, including: structural brain abnormalities (e.g. calcifications, ventriculomegaly, lissencephaly), eye abnormalities, hearing impairment, and other consequences of central nervous system dysfunction (e.g arthrogryposis, clubfoot).[6,12]

Statistical analysis

We compared infant outcomes from the prospective cohort study of women infected with ZIKV during pregnancy,[12] with those from the cross-sectional study of women not infected with ZIKV during pregnancy. For both of these ZIKA-DFA-FE study populations only the subset of women and infants from Guadeloupe, were considered. Only outcomes of live born infants were compared due to the unavailability of data on fetal demise in ZIKV unexposed pregnancies where recruitment took place at the time of delivery. Baseline characteristics of women were compared using the Student’s t test for continuous variables and chi-square or Fisher’s exact test for categorical variables. The proportion of live born infants with anthropometric abnormalities and other defects was compared using Fisher’s exact test. The odds ratio (OR) for the association between abnormalities in live born infants and Zika virus exposure during pregnancy was estimated through a multiple logistic regression model that included maternal age, occupational category, and ethnicity. Maternal age was categorized as 18–24, 25–34, 35–39, or 40+ years. Three groups of occupational categories were used: unemployed and student participants; employees and labourers; business owners, highly qualified professionals and intermediate professions (e.g. teachers, nurses). Ethnicity was self-reported by mothers and categorized as follows: any sub-Saharan African or Amerindian ancestry (including those indicating ancestry as ‘Guadeloupe’, ‘Antilles’, or similar), other ancestry (e.g. Indian, North African, South East Asian) without sub-Saharan African or Amerindian ancestry, European ancestry only. Data were analyzed by ALF using Stata 13.1 (StataCorp LP Lakeway, TX, USA).

Results

Participants

Of the 1484 women enrolled in the cross-sectional study in Guadeloupe, 484 had a negative IgG serology test for ZIKV at the time of delivery. Of these women, 395 additionally had ZIKV IgM testing, and one woman had ZIKV PCR testing, on the blood sample taken at the time of delivery—all results were negative. Of these 484 women, 6 had twin pregnancies and therefore the outcomes of 490 live born infants were observed. In the prospective cohort, of the 250 pregnant women in Guadeloupe who had symptomatic, RT-PCR confirmed ZIKV infection at any time during pregnancy, 245 pregnancies were followed up until the time of the pregnancy outcome. Within this group there were eight cases of fetal demise and four sets of twins, and therefore the outcomes of 241 ZIKV exposed live born infants were observed. See Fig 1.

[Figure omitted. See PDF.]

Fig 1. Flow chart of inclusion of ZIKV un-exposed and exposed pregnant women for inclusion of live births in this analysis, Guadeloupe, 2016.

https://doi.org/10.1371/journal.pntd.0009048.g001

The mean age of ZIKV non-infected women was 30.7 years (SD = 6.4), and that of ZIKV infected women was 30.0 years (SD = 6.3). There was a higher proportion of reported smoking in the ZIKV-infected cohort during pregnancy compared to the ZIKV non-infected: 4.2% (95%CI: 2.0–7.6%) versus 0.6% (95%CI: 0.4–1.8%). There were also more unemployed women in the ZIKV non-infected group compared to the ZIKV-infected one: 48.1% (95%CI: 43.3–52.4) versus 34.6% (95%CI: 28.6–41.0). See Table 1.

[Figure omitted. See PDF.]

Table 1. Baseline characteristics of ZIKV non-infected and infected12 women from Guadeloupe who delivered live born infants, 2016.

https://doi.org/10.1371/journal.pntd.0009048.t001

Anthropometric abnormalities and other birth defects in live born infants

Of the 490 live born infants of women without ZIKV infection during pregnancy, 66 (13.5%, 95%CI: 10.6–16.8) were small for gestational age, and 41 (8.4%, 95%CI: 6.1–11.2) had microcephaly. One of these cases of moderate microcephaly had a possible genetic aetiology (Adams Oliver syndrome). None of the 41 cases of microcephaly were identified as such by the attending clinicians (i.e. they were defined later after comparing infant measurements to a standardized growth curve) and for none were there reports of other structural brain or clinical abnormalities. Additionally, one infant (0.2%, 95%CI: 0.01–1.1) had an abnormality that could be a consequence of CNS dysfunction, which was clubfoot. Five infants (1.0%, 95%CI: 0.3–2.4) had other abnormalities that are not considered as linked to ZIKV infection, including: supplementary fingers or toes (n = 2), anal imperforation (n = 1), urinary tract abnormalities (n = 2). Besides two infants born to HIV-infected mothers who were small-for-gestational-age, there were no other abnormalities identified in the remaining four infants born to mothers with TORCH infections. See Table 2.

[Figure omitted. See PDF.]

Table 2. TORCH results in ZIKV non-infected and ZIKV-infected [12] women giving birth in Guadeloupe during or up to 9 months after the 2016 ZIKV epidemic period (2016–2017).

https://doi.org/10.1371/journal.pntd.0009048.t002

There was no significant difference in risk of anthropometric or other mild birth defects in live born infants whose mothers had a symptomatic PCR-confirmed ZIKV infection during pregnancy compared to those whose mothers had no evidence of prior ZIKV infection at the time of delivery in Guadeloupe (6.6%, 95%CI: 3.8–10.6, versus 8.6%, 95%CI: 6.2–11.4, respectively). See Table 3.

[Figure omitted. See PDF.]

Table 3. Abnormalities in live births of ZIKV non-infected and infected [12] women in Guadeloupe during or up to 9 months after the 2016 ZIKV epidemic period.

https://doi.org/10.1371/journal.pntd.0009048.t003

There was no association (OR 0.8, 95%CI: 0.4–1.4) between ZIKV exposure and abnormalities in live born infants in a multiple logistic regression model adjusting for age, occupation, and ethnicity. When compared to women 25–34 years of age, women 18–24, 35–39, and 40 or more years of age were more likely to have a live born infant with abnormalities with ORs of 5.1 (95%CI: 2.5–10.7), 2.3 (95% CI: 1.0–5.0) and 2.9 (95% CI: 1.0–8.0), respectively. There was no association between either occupation or ethnicity and the likelihood of having a live born infant with abnormalities. See Table 4.

[Figure omitted. See PDF.]

Table 4. Association of Zika virus exposure during pregnancy and other maternal characteristics with abnormalities in 731 live born infants.

https://doi.org/10.1371/journal.pntd.0009048.t004

Of the 16 abnormalities seen among 241 live born infants of women with ZIKV infection during pregnancy (Table 3), 14 of these were either isolated anthropometric abnormalities (i.e. measurement-based microcephaly) or isolated mild CNS dysfunction defects (i.e. clubfoot), as well as one case of spina bifida (no longer considered as linked to ZIKV infection[17,18]), and one case of ventriculomegaly.[12] In the original prospective cohort, there were an additional eight pregnancies with known outcomes from Guadeloupe (i.e. a total of 249 infants/fetuses), all of which led to fetal demise and were not included in the current comparative analysis of live born infants (See Fig 1). Of these eight cases of fetal demise, there were two instance of miscarriage and three instances of stillbirth without any evidence of fetal anomalies. The other three instances of fetal demise were terminations of pregnancy for fetal anomalies (TOPFA) that were severe and suggestive of Zika Congenital Syndrome. In our original report, all neurological or ocular birth defects from Guadeloupe that were potentially linked to ZIKV infection in Guadeloupe were included in our risk estimate and so this included the 16 abnormalities in live born infants as well as the three cases of TOPFA (n = 19/249; 7.6%, 95%CI: 4.7–11.7).[12] If, as may be justified by the current study, isolated anthropometric abnormalities and other mild birth defects in live born infants had not been definitely considered as ‘potentially linked to ZIKV’ in the original ZIKV-exposed prospective cohort study, then the number of ZIKV-related abnormalities in live born infants would have been counted as one (i.e. one case of ventriculomegaly). This one case, combined with the severe neurological abnormalities in the three cases of TOPFA, brings our estimate down to 1.6% (95%CI: 0.4–4.1%). This would have translated to a 4.1% (95%CI: 0.9–11.5%), 0.8% (95%CI: 0.02–4.6%), and 0% (one-sided 97.5%CI:0–6.3%) risk of birth defects per first, second, and third trimester, respectively.

Discussion

We found no statistically significant difference in the risk of neurological birth defects in live born infants of ZIKV infected and non-infected women in Guadeloupe during the 2016 epidemic period. This can primarily be explained by the fact that most of the abnormalities reported as ‘potentially linked to ZIKV’, for both the exposed and non-exposed pregnancies in this study, represent identification of isolated microcephaly in live births; these cases were defined based only on anthropometric measurements, with known clinical and radiological findings for each infant being normal.[12] This diagnostic approach to microcephaly, which does not require clinical judgment on the appearance of microcephaly, but relies solely on the comparison of a head circumference measurement against a normalized birth curve, has been used in all of the prospective cohort studies describing the risk of birth defects following maternal ZIKV exposure during pregnancy, to date.[10–15] However, defining microcephaly based on ‘metrics’ does not reflect the real-life clinical diagnosis of this condition, and can lead to a false surge in cases if applied to an entire population for surveillance purposes.[19] Registries using more stringent definitions (e.g. -3SD) and/or clinician specific criteria indicate that true disease-related microcephaly is very rare; the European Surveillance of Congenital Anomalies (EUROCAT) recently estimated the prevalence of microcephaly in Europe to be 1.53 per 10,000 births (~0.02%) with data from 2012–2016.[20] As infant growth is approximately normally distributed, the INTERGROWTH-21st study itself prescribes that approximately 2% and 0.1% of healthy infants should have a head circumference at birth that falls below -2 and -3SD, respectively, on their pooled international growth standard.[16] The INTERGROWTH-21st study noted varying levels of fit for individual populations when compared to their pooled standard,[16] which could exacerbate the proportion of otherwise normal infants falling below these thresholds.

This is the largest study of ZIKV non-infected women from a defined epidemic region that has been used as a comparative control group against ZIKV-infected pregnant women followed up during pregnancy. It was conducted in a resource-rich setting where the standard of care during pregnancy is high. The exposure statuses of each of the two groups included were well defined. The ZIKV infected women from Guadeloupe were confirmed via RT-PCR within days of infection.[12] Relying solely on PCR testing for defining the ZIKV-exposed group avoided difficulties in interpreting serological results in a region where other flaviviruses co-circulate. The ZIKV non-infected group was defined so based on the absence of ZIKV IgG at the time of delivery. ZIKV IgG appears rapidly after infection and remains detectable for a follow-up of four or more months.[21,22] Several studies have demonstrated 100% sensitivity of the ZIKV IgG Euroimmun assay for detecting antibodies soon after infection and for several months, including: 124 ZIKV-infected individuals in French Guiana sampled between 30 and 180 days after symptom onset;[23] 65 pregnant women from the ZIKA-DFA-FE cohort in Guadeloupe with RT-PCR confirmed ZIKV infection (14 women were infected in the first trimester) sampled from the time of symptom onset up until delivery;[24] and finally, from the manufacturer’s own evaluation.[25] A 100% sensitivity of ZIKV IgG testing at delivery to detect infection during pregnancy translates into a 100% negative predictive value, i.e., women with a negative test at delivery had not been infected during pregnancy.

This study has several limitations. As we had no directly comparable prospective cohort, we used a group of ZIKV non-infected women delivering at the same hospitals and in the same time period. Our aim was not to compare the risk of birth defects from conception to delivery in the two groups, since this information was not available for the ZIKV non-infected group, but to compare the proportion of microcephaly and other birth defects among live born infants, to see if the minor abnormalities found in the ZIKV-exposed group could be confidently related to ZIKV infection. If the ZIKV non-exposed group had been followed prospectively in a similar fashion to the ZIKV exposed pregnancies, this would have allowed for a more complete comparison of the risk of abnormalities and adverse outcomes. There is limited recent baseline data on the incidence of pregnancy loss in Guadeloupe, specifically. One 2004 study from centres across France, including Guadeloupe and Martinique, found an overall TOPFA incidence at any gestational age of 0.7%.[26] In 2005 in Paris, the incidence of TOPFA after 26 weeks gestation was estimated as 0.2%.[27] The Pan American Health Organization reported the incidence of stillbirth among women in Guadeloupe (2001–2003) to be 1.6%, with a decreasing trend.[28] The French Pregnancy Cohort found an incidence of 18.6% and 0.7% for miscarriage and stillbirth across France (2010–2013), respectively.[29] Of 249 fetuses/infants in our Zika virus exposed cohort, there were three instances each of stillbirth and TOPFA (each 1.2% (95%CI: 0.3–3.5), as well as two miscarriages (0.8% (95%CI: 0.1–2.9). Therefore, our incidence of stillbirth seems comparable to previous findings, whereas our incidence of TOPFA may be similar or slightly higher. Miscarriage incidence is artificially low in our Zika virus exposed cohort as participants were recruited at varying stages of pregnancy. The exposed and unexposed groups were similar in terms of the prevalence of TORCH infections as well as for most baseline characteristics; however, ZIKV non-infected women had more unemployment, and more ZIKV infected women reported smoking during pregnancy. This may reflect recall ability and employment situation differences according to the timing of data collection, as ZIKV non-infected women were all recruited at the time of delivery and ZIKV infected women were recruited at various earlier time points during their pregnancy. Furthermore, the quality of follow-up and collection of data on the pregnancy was higher in the prospective ZIKV-exposed symptomatic cohort. Highlighting this is the fact that ultrasound records were available for 88.4% of ZIKV infected women and only 51.6% for ZIKV non-infected women. However, such a difference would most likely lead to an underestimation of birth defects in the ZIKV non-infected group. Furthermore, the completeness of data at the time of delivery for live births, which was used to determine anthropometric and clinically apparent abnormalities, was very high in both ZIKV-exposed (97.9%) and non-exposed (98.8%) infants. It is also important to note that in the ZIKV-exposed infants in Guadeloupe, third trimester prenatal ultrasound results which could confirm a lack of underlying structural brain abnormalities, were not available for 3 of 11 infants (27%) who are identified as having ‘isolated microcephaly’.[12] The mothers of these infants were infected with ZIKV in the first trimester (n = 1), second trimester (n = 1), and third trimester (n = 1). If any of these infants had underlying structural brain abnormalities, such as calcifications, then our stated adjusted risk of birth defects linked to ZIKV would be an underestimate. A further limitation of our study is our inability to include the risk of some abnormalities that may be detected at a later stage of the infants’ lives, such as ocular defects. Only one prospective cohort study to date has given such an estimate: 6.0% in Brazil.[10] This risk estimate is unlikely to apply to live born infants in our setting; all infants with severe ocular defects (such as macular lesions) in the prospective Brazilian cohort had severe structural brain abnormalities, including microcephaly and calcifications, detected by ultrasound prenatally, and in our setting, all fetuses with severe structural brain abnormalities detected prenatally were medically aborted. One live born infant in our ZIKV-exposed group did have moderate structural brain abnormalities detected prenatally (i.e. ventriculomegaly), in this infant, an eye examination after birth showed no abnormalities. Finally, various effect modifiers, such as socioeconomic status and previous infection with other arboviruses, have been proposed to potentially increase the risk of Zika Congenital Syndrome when women are infected with ZIKV during pregnancy.[30–32] It would be reasonable to believe that such factors could also lead to an increased risk for mild and anthropometric abnormalities regardless of ZIKV infection. Although our multiple logistic regression did not find any association of abnormalities in live born infants with occupational category or ethnicity, other indicators of socioeconomic status (e.g., household income, education level) were unmeasured. Additionally, very little dengue virus testing was done. Therefore, this study is not able to explore the differences in prevalence of past or current dengue virus infection between the ZIKV-exposed or unexposed groups, or to determine the effect that this may have on the incidence of abnormalities in live born infants.

This study highlights the importance of a control group for establishing the baseline risk of anthropometric and other birth defects when determining the risk of congenital abnormalities that can be linked to a given infection during pregnancy. This is particularly true for abnormalities defined by anthropometric measurements, where regional variations may exist;[18,33–35] in these instances, the use of regionally specific growth standards as well as standardized international growth standards would be of interest. When a control group comparison is not possible, published baseline estimates from a pre-infection (e.g., pre-Zika virus) time period may be useful for contextualizing findings. However, the compatibility of the definitions used for birth defects in previous literature with those of any current study should be scrutinized prior to ‘before and after’ comparisons. For example, the Latin American Collaborative Study of Congenital Malformations, which relies on reporting of microcephaly to birth defects registries, determined a microcephaly incidence of 0.05% in Brazil between 2010 and 2014.[19] However, another study in two regions of Brazil in 2010 used a metric microcephaly definition with the INTERGROWTH-21st standards and found incidences of 2.5% and 3.5%.[36]

In our case, reassessment of the risk of birth defects from a ZIKV exposed prospective cohort after consideration of mild abnormalities seen in a time and place-matched control group, indicates an initial significant overestimation of the risk of birth defects potentially associated with ZIKV at the time of birth. Our new estimates of approximately 4%, 1%, and 0% for the risk of birth defects following ZIKV infection in first, second, and third trimester, respectively, are comparable to those from a recent meta-analysis of prospective studies on this topic.[37] Still, as with other congenital infections that cause neurological abnormalities, such as cytomegalovirus and rubella,[38,39] longer term studies that postnatally follow-up infants exposed to ZIKV in-utero, but who are apparently healthy at birth, are needed in order to understand additional ocular, hearing, and developmental abnormalities and derive the true overall risk of defects. For these latter infant cohorts, consideration of the proportion of hearing and developmental abnormalities, which are non-invasive examinations, in a ZIKV non-exposed control group, through testing performed with the same vigilance, will continue to be of major importance.

Acknowledgments

We would like to acknowledge all of the women and their infants who participated. We are grateful for the support of Jacqueline Deloumeaux and Joelle Colat-Peyron, from Karubiotec the Centre de Ressources Biologiques. We would also like to acknowledge key medical personnel from the participating maternities, including: Nicole Alcindor, Marie-Laure Ametis, Gülen Ayhan, Laetitia Banco, Dimitri Beltou, Colette Danquin, Véronique Davidas, Sébastien Desbois, Aline Feriaux, Livia Gabriel, Chimène Geoffroy, Cecile Gravelot, Isabelle Guerry, Audrey Hedreville, Eustase Janky, Louise Kickza, Xavier Legros, Candice Mancliere, Cécile Marie-Joseph, Nelly Monpierre, Raissa Pierre-Justin, Véronique Procida, Sabine Robier, Catherine Ryan, Karine Samar, Maité Segretier, Marie-Paule Theobald, Teddy Toto, Zoé Vierzac. In addition, we thank Kébé Beavogui, Alexandrine Eustache, Valérie Rondoff, Marie-Claude Panol, Marie-France Miranne, Céline Rocquet, Laure Jacoby-Kaoly Alexandre, and Myriam Atine, for their administrative support.

Citation: Funk AL, Hoen B, Vingdassalom I, Ryan C, Kadhel P, Schepers K, et al. (2021) Reassessment of the risk of birth defects due to Zika virus in Guadeloupe, 2016. PLoS Negl Trop Dis 15(3): e0009048. https://doi.org/10.1371/journal.pntd.0009048

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