Abstract
Systematic review registration: PROSPERO CRD42020199225.
In this article
- INTRODUCTION: Gestational diabetes mellitus (GDM) is defined as the onset or first recognition of glucose intolerance during pregnancy, primarily in the second or third trimester. 1 GDM is one of the most common metabolic complications in pregnancy, affecting 5%–25% of all pregnant women worldwide, depending on screening approaches and diagnostic criteria.
- MATERIALS AND METHODS: We performed a systematic review and meta‐analysis of epidemiological studies examining the association between components of MetS and risk of GDM. The review was performed according to the PRISMA 2020 Guidelines (Preferred Reporting Items For Systematic Reviews and Meta‐analyses).
- CONCLUSION: The meta‐analysis provides some evidence that early pregnancy assessment of FPG or the MetS, as a clustering of factors, offers a potential opportunity to detect and treat individual risk factors as an important approach towards GDM prevention. Women with overweight or obesity in pregnancy are also at risk for GDM, however weight loss in pregnancy…
Opening sentences of each section, unchanged.
INTRODUCTION
Gestational diabetes mellitus (GDM) is defined as the onset or first recognition of glucose intolerance during pregnancy, primarily in the second or third trimester. 1 GDM is one of the most common metabolic complications in pregnancy, affecting 5%–25% of all pregnant women worldwide, depending on screening approaches and diagnostic criteria. 2 GDM has adverse maternal health consequences, including an increased risk for hypertensive disorders of pregnancy, preterm delivery, medicalised delivery, 3 , 4 as well as an increased risk for developing type 2 DM and cardiovascular events in the first decade following pregnancy. 5 , 6 Offspring of mothers with GDM are at greater risk for large for gestational age, 7 , 8 , 9 respiratory distress syndrome 10 and neonatal hypoglycaemia, 11 and tend to develop type 2 diabetes at younger ages. 12
Recognised risk factors for GDM include maternal obesity, advanced maternal age, excess gestational weight gain, Asian and African ethnicity, and a history of diabetes. 13 , 14 , 15 , 16 , 17 Fasting or postprandial blood glucose may be assessed early, but whether it is a suitable screening test for GDM has not been clarified. 18 , 19 , 20
Metabolic syndrome is a clustering of cardiovascular risk factors that includes atherogenic dyslipidemia, raised blood pressure, insulin resistance, and obesity, 21 increasing the risk of cardiovascular disease (CVD) 22 and diabetes by up to 5‐fold. 23 In two pregnancy cohorts, Grieger et al. 24 and Schneider et al. 25 showed that MetS, measured in early pregnancy, increased the risk for GDM by 2–4 fold, even after adjusting for body mass index (BMI). Several studies have demonstrated that individual metabolic markers such as raised triglycerides (TG) or low density lipoprotein cholesterol, or reduced high density lipoprotein cholesterol (HDL‐C) pose a significant risk for developing GDM. 26 , 27 , 28 The relationship between MetS or its individual components as a risk factor for GDM is plausible given their shared relationship to future risk of CVD. Importantly, metabolic factors can be modified by diet, lifestyle 29 , 30 and pharmacological agents. 31 Consideration of assessing metabolic markers in early antenatal care may provide information about potential future risk for GDM, allowing for early detection and management.
While some systematic reviews have been conducted on similar topics, they did not specifically examine MetS factors, but rather explored biomarkers associated with placental pathology, 32 central obesity, 33 and predictive 34 or diagnostic biomarkers for metabolic diseases. 35 To date, there has been no systematic review or meta‐analysis comprehensively evaluating whether MetS or its components, measured in early pregnancy, associate with risk for GDM. This would be important given the current controversies surrounding early screening of GDM using conventional risk factors, and that intervention studies aimed at preventing GDM, predominantly through targeting hyperglycemia, have not been consistently successful. 36 Measurement of MetS or its components may offer a new approach to identify potential risk for GDM, and which could be used as a complementary component to standard routine antenatal care.
The aim of this systematic review and meta‐analysis is to comprehensively evaluate the association between MetS and its components, measured in early pregnancy, and risk for GDM.
MATERIALS AND METHODS
We performed a systematic review and meta‐analysis of epidemiological studies examining the association between components of MetS and risk of GDM. The review was performed according to the PRISMA 2020 Guidelines (Preferred Reporting Items For Systematic Reviews and Meta‐analyses). 37 The study protocol was registered on PROSPERO (International Prospective Register of Systematic Reviews) under the identification code: CRD42020199225 and is available online (www.crd.york.ac.uk/prospero).
Selection criteria and search strategy
Potential studies were identified through electronic database searches on Cumulative Index to Nursing and Allied Health Literature, PubMed, Embase, and the Cochrane database, and manual searches of potentially eligible references in review articles. The search strategy included a combination of subject indexing terms (i.e., MeSH) and free text search terms relating to early pregnancy, prognostic factors, and GDM, along with search filters recommended for prognostic modelling. 38 The search strategy was iteratively developed by Jessica A Grieger and Nahal Habibi in consult with an academic librarian. The last search was performed on 5 May 2021. The full search strategy is provided in the Supporting Information.
The PICOTS criteria was used to define the aim, search strategy, inclusion and exclusion criteria, that is Population (Pregnant women), Index (Components of the MetS and MetS as a cluster), Comparator (Unexposed group [non GDM women]), Outcome (GDM measured at 24–28 weeks' gestation), Timing (recruitment <16 weeks' gestation), Setting (Antenatal care). The index prognostic factors included the following MetS factors: waist circumference (WC; abdominal obesity), systolic/diastolic blood pressure, glucose, glycated haemoglobin (HbA1c), TG, or HDL‐C, and MetS as a cluster. 39 , 40 , 41 BMI was also examined because the International Diabetes Federation criteria for MetS includes BMI as a surrogate measure for WC. Excluded studies were those examining diagnostic models; animal models; pregnancy outcomes in women after GDM diagnosis; or studies assessing measurements that are not assessed routinely in antenatal care (e.g., using bioelectrical impedance assay).
Core outcomes
The primary outcome was GDM using any diagnostic criteria, measured at 24–28 weeks' gestation.
Study selection, data collection and risk of bias assessments
All citations were imported into an Endnote file, duplicates were removed, and the remaining articles export into the Rayyan software database for blind screening. 42 Title and abstract screening was completed in duplicate by two authors independently (Jessica A. Grieger, Prabha H. Andraweera, Molla Wassie, Mahnaz Bahri Khomami, Tina Bianco‐Miotto, Jared Vandersluys, Shao J Zhou, Nahal Habibi, Aya Mousa), and any disagreements were resolved by consensus between the two authors. Where necessary, authors of included articles were contacted to provide missing information and/or unpublished data.
Data extraction was performed by at least two authors independently (Nahal Habibi, Rhiannon K. Patten, Aya Mousa, Chau Thien Tay, Prabha H. Andraweera, Mahnaz Bahri Khomami, Molla Wassie, Jared Vandersluys, Ali Aflatounian), using a specifically designed Microsoft Excel spreadsheet. Cross‐checking and resolving of differences were completed by Jessica A. Grieger. Data extraction was guided by CHARMS‐PF (Critical Appraisal and Data Extraction for Systematic Reviews of Prediction Modelling Studies): a checklist of key items to be extracted from primary studies of prognostic factors. 43 Data extraction included: author, year, country; type of study; study population and sample size; study duration and month/year the study was carried out; inclusion criteria; exclusion criteria; GDM diagnosis and time point; exposures in the model; and statistical adjustments. When risk estimates from more than one multivariable analysis were reported, data were extracted from the analysis adjusting for the largest number of confounders. If risk estimates from other routine antenatal factors were reported, only risk estimates related to MetS were extracted. Only standard cut‐off values for categorical data were used, for example, the World Health Organization (WHO) categories for BMI. Outcome data reported as odds ratios (OR)/relative risks (RR) and 95% confidence intervals (CIs) were the primary output of interest.
Risk of bias assessment at the study‐level was performed independently by two researchers, using the quality in prognostic factor studies (QUIPS) Risk of Bias tool. 43 The same two independent authors who completed the data extraction completed the risk of bias for the same set of studies. Domains included study participation; study attrition; prognostic factor measurement; outcome measurement; adjustment for other key prognostic factors; and statistical analysis and reporting. Each domain was judged as low, moderate or high risk, with more weighting given to the domains of ‘Adjustment for other prognostic factors’ and ‘Statistical analysis and reporting’, due to the observational nature of the included studies. Pilot testing was performed using three test articles to ensure consistency between the authors prior to formally commencing risk of bias assessments. For each study, the item scores were collated and an overall risk of bias (low, moderate, and high) was determined.
Data analysis
All analyses were conducted using Review Manager (V5.4.1). For the primary meta‐analyses, studies reporting OR or RR with 95% CIs were analysed as these data are best suited to address questions on prognosis. Data were pooled using the restricted maximum likelihood random‐effects models to account for heterogeneity among the studies and outcome measures. 44 Unadjusted analyses were firstly reported followed by adjusted analyses with a core set of prognostic covariates (maternal age, maternal BMI, family history of diabetes, ethnicity). As many of the included studies did not adjust for all four covariates, we opted for at least one core covariate in each model.
Heterogeneity was quantified using the I 2 statistic. Significance for heterogeneity was set at p < 0.10, with an I 2 > 50% considered to be of relatively high heterogeneity. 45 Sources of heterogeneity were explored where outlier study/s were eliminated from the meta‐analysis in a series of sensitivity analyses and the effect size was recalculated to determine the influence of those studies. 46 We considered outlier studies that had a different direction of effect, a high effect size, or studies judged to be at high risk of bias. 45 If ≥10 studies were available, we assessed publication bias by visual inspection of funnel plots. 47 Data reported as mean and SD/SE or 95% CI, or as median and interquartile range were included in the narrative synthesis.
Patient and public involvement
This study was a systematic review and therefore did not include patients as study participants.
RESULTS
Study selection and characteristics
The systematic search identified 7213 articles of which 106 were duplicates, 7029 were ineligible, leaving 78 articles in the systematic review and 40 articles in the meta‐analysis (Figure 1). Characteristics of the included studies are reported in Table 1. The majority of studies were conducted in China (k = 18 studies), USA (k = 9 studies), UK (k = 8 studies), and Australia (k = 8). Study population sizes ranged from 107 48 to 132,899 participants. 49 Of the 78 studies included, the majority (41.25%) reported on two or more MetS factors. Body mass index was the most common independently assessed risk factor (64.1%), while 10 studies (12.8%) reported on HbA1c and HDL‐C.
FIGURE 1 PRISMA flow diagram (Figure not reproduced here; see the original article.)
| Author, country | Type of study | Study population and sample size | Years | Inclusion criteria | Exclusion criteria | GDM diagnosis and time point | Main exposure in model (e.g., BMI, TG) | Adjustments made |
|---|---|---|---|---|---|---|---|---|
| Madhavan 2008, India | Prospective cohort | Outpatients of Ob/Gyn Department, Government Medical College Hospital, Kottayam, Kerala. Enroled during first antenatal visit n = 106; GDM n = 8 | April 2005–April 2006 | Single live intrauterine pregnancies; gestational age ≦12 weeks' gestation; maternal age 18–35 years | History of diabetes pre‐pregnancy, history of drugs known to cause insulin resistance within prior 6 months; history of thyroid or pituitary disorders; comorbid conditions and severe systemic illness | World Health Organization (WHO) 1999 criteria, at 24–28 weeks' gestation. | BMI, waist circumference (WC), waist hip ratio (WHR) and fasting blood sugar | Not reported |
| Cozzolino 2017, Italy | Single centre retrospective cohort study | n = 656 | January 2010–January 2016 | All multiple pregnancies screened for GDM with 75 g, 2 h OGTT at 24–28 weeks' gestation | Maternal pre‐gestational diabetes and hypertension or other chronic diseases (i.e., cardiovascular, autoimmune diseases, inherited and acquired thrombophilia); absence of the 75 g OGTT screening during pregnancy; major foetal congenital anomalies; twin‐to‐twin transfusion syndrome; miscarriage or intrauterine foetal death before the OGTT | International Association of Diabetes and Pregnancy Study Groups criteria (IADPSG), at 24–28 weeks' gestation | BMI | Not reported |
| Hinkle 2018, USA | Nested case control study | Enroled between 8 and 13 weeks' gestation; n = 2802; GDM n = 107, matched non‐GDM controls n = 214 | 2009–2013 | Low‐risk, pregnancies among non‐obese women and 468 pregnancies among obese women (n = 2802 total). The inclusion criteria for obese cohort included women who smoked prior to pregnancy, had a haematologic disorder, or had GDM in prior pregnancy. | Non‐obese women who smoked, had GDM in a prior pregnancy or had a haematologic disorder (e.g., chronic anaemia, sickle cell disease, low platelets, blood clotting problems) were excluded; as were women with HbA1c ≥ 6.5% (48 mmol/mol) at enrolment (n = 3) or who had a haemoglobin variant (n = 6). | Carpenter and Coustan criteria, as endorsed by the American Diabetes Association (ADA), and the American College of Obstetrics and Gynaecologists (ACOG), at 24–29 weeks' gestation. | HbA1c | Maternal age, gestational age at delivery, family history of diabetes, pre‐pregnancy overweight and obesity |
| Zhu 2020, China | Prospective cohort | n = 2949; GDM n = 581 (19.7%) | July 2016–June 2017 | Between 6 and 8 weeks' gestation; aged >18 years; singleton pregnancy; regular prenatal visits; opted to deliver at Fu Xing Hospital | Pre‐pregnancy cardiovascular disease; chronic hypertension; pre‐pregnancy diabetes; thyroid disorder; taking medications known to affect glycaemic and lipid metabolism; twin pregnancy | IADPSG criteria, at 24–28 weeks' gestation | Fasting (>8 h) triglycerides (TG) at 6–8 weeks' gestation; stratified for pre‐pregnancy BMI | Maternal age, fasting blood glucose, pre‐pregnancy BMI, family history of DM |
| Godwin 1999, Canada | Retrospective cohort | n = 1298; GDM n = 110 (8.5%) | 1 January 1987–31 December 1995 | Swampy Cree women who gave birth at Weeneebayko Hospital, Moose Factory, James Bay, Ont. | Women who were transferred to other hospitals (n = 30). Large amounts of data missing | International Workshop‐Conference on Gestational Diabetes; or fasting sugar or a 1‐h 50‐g challenge test was done, resulting in a blood glucose value of ≧7.8 mmol/L. GDM diagnosis time‐point not reported. | Diastolic blood pressure, weight at first visit | Age, history of GDM in a previous pregnancy, diastolic blood pressure, weight at first prenatal visit, first degree relative with GDM |
| Grieger 2018, Australia and New Zealand | Prospective cohort | n = 3126 (55.6% of total population); GDM = 14.7% | November 2004 – November 2011 | Low‐risk, nulliparous women, at 14–16 weeks' gestation with singleton pregnancies recruited from Adelaide (Australia), Auckland (New Zealand), Cork (Ireland), Leeds (UK), London (UK), and Manchester (UK). | High risk for various pregnancy complications, including preeclampsia, small for gestational age or spontaneous preterm birth; took high dose vitamin supplements; type 1 or 2 diabetes | WHO 2013 criteria, at 24–28 weeks' gestation. | Waist circumference (WC), TG, HDL‐C, sBP, dBP, glucose, MetS | Maternal BMI, age, study centre, SEI, ethnicity, foetal sex, physical activity, smoking status, depression status |
| Doi 2020, UK | Retrospective cohort | n = 132,899; GDM n = 1877 (1.42%) | January 2007 – December 2015 | All women within the Scottish Morbidity Record 01 or 02 or Scottish Birth Record with first time singleton deliveries. | Mothers aged below 20 years and over 40 years were excluded (post hoc) | WHO's International Classification of Diseases, Tenth revision (ICD‐10). GDM diagnosis time‐point not reported. | BMI | Maternal age at delivery, smoking during pregnancy, Carstairs 2001 quintiles for socioeconomic status in Scotland |
| Yachi 2011, Japan | Prospective cohort | Pregnant women who visited the obstetrics clinic in Tokyo <13 weeks' gestation, n = 509 | September 2008–January 2010 | Pregnant women who visited the obstetrics clinic in Tokyo <13 weeks' gestation and without recognised diabetes prior to pregnancy | Fasting plasma glucose (FPG) levels <2.5 mmol/l (n = 3). Missing or incomplete blood glucose data (n = 15). | Japan Society of Obstetrics and Gynaecology criteria, at 24 –29 weeks' gestation. | BMI, FPG | Maternal age, parity, BMI at first prenatal visit, gestational weight gained per week up to GCT. |
| Iyoke 2013, Nigeria | Nested case control study within a retrospective cohort | All booked parturient women who delivered at three major maternity centres; n = 648; early pregnancy obesity n = 324; control (normal weight) n = 324 | 1 January 2010–31 December 2011 | Cases: Parturient women with BMI ≥30 kg/m2 | n = 16 obese women refused to be included in the study. Only included obese women and matched controls. | Not reported. | BMI | Not reported |
| Controls: Parturient women who booked in the first trimester with normal BMI and matched with cases in age and parity. | ||||||||
| Schrauwers 2009, Australia | Retrospective cohort | Singleton pregnancies at the Lyell McEwin Hospital, South Australia n = 370 | January 2006–June 2006 | Singleton pregnancies delivered at Lyell McEwin Hospital, Adelaide with complete medical records. | Not reported | Case records; no other data reported. | BMI | Not reported |
| Migda 2016, Poland | Prospective observational | Cases: Caucasian women in singleton pregnancies (n = 124) between 11 and 13 weeks' gestation with metabolic syndrome (MetS). | 2011–2013 | Single, live pregnancy and 3 of 5 risk factors: Population‐specific elevated WC; drug treatment for elevated TG or elevated blood pressure or elevated fasting glucose; reduced high density lipoprotein cholesterol (HDL‐C) <40 mg/dl (1.0 mmol/L) in males and <50 mg/dl (1.3 mmol/L) in females. Controls: 30 women with healthy pregnancies. | Not specified but they included 124 cases from the total of 127 cases. | Polish Gynaecology Society criteria, at 24–28 weeks' gestation | MetS | Not reported |
| Controls (n = 30): Healthy pregnant women | ||||||||
| GDM, n = 19 | ||||||||
| Kouhkan 2018, Iran | Nested case‐control | Singleton pregnancies n = 270; GDM n = 135, controls n = 135 | October 2016–June 2017 | ART singleton pregnancy, aged 20–40 years | Pre‐existing diabetes; multiple pregnancy and chronic diseases such as hypertension, cardiovascular diseases, untreated thyroid disease, liver diseases, renal diseases, autoimmune diseases, and connective tissue disorders; those taking corticosteroids | ADA/IAPDSG criteria, at 24–28 weeks' gestation | Fasting blood sugar, blood pressure | Age and BMI, family history of diabetes, and gravidity |
| Phaloprakarn 2009, Thailand | Retrospective cohort | Cohort 1 n = 1876; GDM n = 586 (31.2%) Cohort 2 (validation cohort) n = 1900; GDM n = 469 (24.7%) | Cohort 1 March 2005–October 2006. Cohort 2 July 2007–December 2005 | Both cohorts; singleton pregnancy, no overt diabetes, certain last menstrual period (LMP), first trimester (14 weeks' gestation) | Not reported | Carpenter and Coustan criteria, at 24–28 weeks' gestation | BMI | Age, parity, family history of diabetes, prior macrosomia, history of ≥2 abortions |
| Sweeting 2017, Australia | Retrospective case control | n = 978; GDM n = 248, non‐GDM n = 730 | April 2011–May 2013 | Singleton pregnancy; attending Royal Prince Alfred Hospital, Sydney; at 11 –13 + 6 weeks' gestation | Pre‐existing diabetes; pre‐eclampsia; multiple pregnancies; pre‐term delivery (<37 weeks' gestation); miscarriage; stillbirth; termination; foetal chromosomal abnormality; missing clinical data; where GDM was diagnosed based on a glucose challenge test alone | Australasian Diabetes in Pregnancy (ADIPS) diagnostic criteria, at 24–28 weeks' gestation | BMI | Previous GDM, family history of diabetes, age, south/east Asian ethnicity, parity. |
| Gur 2014, Turkey | Prospective cohort | n = 106; included n = 94 | January 2012–January 2013 | Maternal age 18–40 years; singleton 4–14 weeks' gestation | Pregnant subjects with type 1 or 2 diabetes; hypertension; any additional metabolic disease; on chronic drug therapy; newly diagnosed type 2 diabetes based on GCT and OGTT during the study (n = 6); lost to follow up (n = 6) | National Diabetes Group criteria, at 24 weeks' gestation. | WC, BMI, BP, glucose, total cholesterol (TC), TG, HDL, LDL, insulin, homoeostasis model assessment‐insulin resistance index (HOMA‐IR) | Maximum pre‐peritoneal visceral fat, minimum subcutaneous fat and BMI |
| Lei 2016, China | Prospective cohort | n = 5535; GDM n = 1138 (20.56%) | January 2012–December 2014 | If they attended before 20 weeks' gestation (mean 16 weeks) | Multiple pregnancy, conception by means of gonadotropin ovulation induction or in vitro fertilisation, ischaemic heart disease, stroke, peripheral vascular disease, dyslipidemia, diagnosis of diabetes or/and hypertension before current pregnancy | IADPSG criteria, at 24–28 weeks' gestation. | BMI, fasting plasma glucose, HDL‐C and TG, blood pressure | Maternal age and parity |
| Zhu 2019, USA | Prospective cohort study followed by a nested case‐ control | n = 1839; Screened GDM | Pregnancies delivered as of August 2016 | Multi‐racial/ethnic pregnant women, aged 18–45 years, <11 weeks' gestation | Multiple gestations, pre‐existing diabetes, cancer, hepatitis C, liver cirrhosis, pregnancy termination, diagnosis of diabetes/use of diabetes medication before baseline examination, missing WC or HC data (n = 9) | Carpenter and Coustan criteria, at 24–28 weeks' gestation | BMI, WC | Risk estimates were adjusted for gestational age at waist and hip circumference measurement |
| n = 1759; final cohort sample n = 1750, GDM n = 186 (10.6%) nested case‐control study: GDM n = 115, matched controls n = 230 | ||||||||
| Zhu 2013, China | Prospective | n = 17,186; GDM n = 3002 (17.5%) | January 1 – 29 February 2012 | All women registered to clinic during those times whose blood glucose test results were linked to gestational week. | Pre‐existing diabetes | Criteria established by Ministry of Health China. Diagnosis with meeting or exceeded 75 g OGTT: 0 h (fasting), 5.10 mmol/L; 1 h, 10.00 mmol/L; and 2 h, 8.50 mmol/L. 24–28 weeks' gestation | FPG | Not reported |
| Zhang 2019, China | Prospective observational | n = 1704; GDM n = 544 (37.2%) | March 2017–September 2017 | Healthy women; natural conception; singleton pregnancy; gestational age 8–12 weeks' gestation | Type 1 and 2 diabetes prior to pregnancy; fasting plasma glucose >7 in 1st trimester; cardiovascular diseases; inherited metabolic diseases or thyroid diseases | IADPSG criteria, at.24–28 weeks' gestation | TG, HDL‐C (also TC and LDL‐C) | Maternal age, pre‐pregnancy BMI, gravidity, parity, history of GDM, family history of DM, maternal education, family income, exercise habits pre‐pregnancy, exposure to passive smoking before/during pregnancy, energy intake and expenditure. |
| Magann 2013, Australia | Retrospective cohort study | n = 4490; GDM BMI < 25 kg/m2 n = 2.8% | January 2007–July 2008 | Initial antenatal visit in 1st trimester; singleton pregnancies >20 weeks' gestation | Not reported | Not reported | BMI | Maternal age, nulliparity, ethnicity, pre‐existing diabetes, pre‐existing hypertension, pregnancy weight gain |
| Zhao 2014, China | Retrospective cohort | n = 411; GDM n = 52 (12.7%) | 2010–2011 | Not reported | Not reported | Not reported | BMI, TG | Maternal age |
| Simko 2019, Slovakia | Retrospective cohort | n = 7122; maternal underweight n = 741 (10.4%), normal weight n = 5400 (76.0%), overweight n = 602 (8.5%), obese n = 358 (5.0%) | 1 January 2013–31 December 2015 | Singleton deliveries >37 weeks' gestation | Pregnancies with chronic hypertension; foetal anomalies; type 1 and 2 diabetes | 50 g OGTT at 24–28 weeks' gestation: Fasting and 2 h post 75 g OGTT values were >5.5 mmol/I and >8 mmol/l, respectively. No other criteria/guideline reported. | BMI | Maternal age, gestational age, gestational weight gain, smoking |
| O'Malley 2020, Ireland | Prospective observational cohort | Women with at least one maternal risk factor for GDM n = 202; GDM n = 108 (53.5%) | October 2017‐ November 2018 | Maternal age ≥18 years; understood English; ≥1 maternal risk factor for GDM | Multiple pregnancy; pre‐existing diabetes mellitus. | WHO 2013 criteria, at 26–28 weeks' gestation. | Obesity (no BMI reported), TG, HDL‐C (non‐MetS = TC, LDL‐C, TG:HDL‐C ratio) | Pre‐pregnancy BMI |
| Wang 2016, China | Retrospective cohort | n = 5218; GDM n = 1053 (20.2%) | 20th June–30th November 2013 | Live‐born singleton infant; full information on early pregnancy lipid profiles (14 weeks' gestation); pregnancy course and outcome | Pre‐existing diabetes; hypertension; thyroid disease or immune system disorders; multiple births; missing data on major items such as pre‐pregnancy weight, height, 75 g OGTT results, PE diagnosis, birth weight and gestational age | 75 g OGTT >24 weeks' gestation. Diagnosis of GDM made when any one value met or exceeded the following values: 0 h, 5.1 mmol/L; 1 h, 10.0 mmol/L; 2 h, 8.5 mmol/L. | TG, HDL‐C (also TC and LDL‐C) | Maternal age, pre‐pregnancy BMI, gravidity, parity, education, family history of diabetes, gestational age at time of lipid measurement. Used to estimate ORs for the associations between GDM and early pregnancy lipid levels. |
| El‐Gilany 2010, Saudi Arabia | Prospective cohort | n = 787; GDM n = 30 (3.8%) | 2007 | All women attending PHCCs for antenatal care within the first month of pregnancy and willing to come for regular follow‐up throughout pregnancy | Any pre‐pregnancy chronic medical disease (e.g., hypertension, diabetes, renal or cardiac disease, sickle cell disease), multiple pregnancies | Not reported | BMI | Not reported |
| Wen‐Yuan 2016, China | Prospective population‐based cohort | Chinese women pregnant at 28–37 weeks' gestation; n = 934; GDM n = 71 (7.6%) | June 2010–June 2011 | Pregnant at 28–37 weeks' gestation; integrated medical records and clear gestational age; singleton pregnancy; naturally conceived | Multiple pregnancy; diabetes; chromosomal abnormalities; inherited metabolic diseases or thyroid diseases before pregnancy; experienced serious infection during early pregnancy; conceived with assisted reproductive techniques | IADPSG criteria, at 24–28 weeks' gestation | Fasting bloods taken at 7–10 weeks' gestation for TC, TG, HDL‐C and LDL‐C concentrations, maternal pre‐pregnancy BMI (WHO categories (41)) | Maternal age, pre‐pregnancy BMI, gestational weight gain, parity, maternal education, socioeconomic status, infant sex and delivery mode, family income, smoking |
| Denison 2014, UK | Retrospective population‐based cohort | <16 weeks' gestation recruited n = 109,592 (124,280 deliveries); GDM n = 503 (4.4%). | January 2003–February 2010 | Maternal BMI recorded <16 weeks' gestation; weight 35–140 kg | >140 kg, >44 weeks' gestation, birth weight >6 kg, BMI assessed >16 weeks' gestation | Scottish morbidity records 2 (SMR02) held at ISD of NHS Scotland. No time point recorded. | Maternal BMI <16 weeks' gestation, grouped according to WHO BMI categories (41). | Maternal age, smoking, Carstrairs quintile |
| Han 2018, China | Prospective population‐based cohort | n = 17,803; GDM n = 1383 (7.8%) | October 2010–August 2012 | Women registered with primary care hospital at <12 weeks; non‐fasting 50 g 1 h GCT at 24–28 weeks' gestation | Did not undergo GCT; positive GCT but did not undergo formal OGTT; had pre‐existing diabetes | IADPSG criteria, at 24–28 weeks' gestation. | BMI, WC | Maternal age, height, family history of DM in 1st degree relatives, GA at registration, parity ≥1, education >12 years, Han nationality, non‐singleton pregnancy, SBP at registration, weight gain per week from registration to GCT, smoking and drinking status before pregnancy, BMI, WC |
| Pazhohan 2019, Iran | Prospective | 24–29 years 48.5% of study cohort was overweight or obese. n = 954; control n = 778, GDM n = 176 | August 2014–February 2016 | Singleton pregnancy at 1st trimester; attended health centres for first prenatal visit and invited to participate in the study; blood sampling at 9 weeks' gestation | Type 1 or 2 diabetes pre‐pregnancy; FPG ≥126 mg/dl in the first trimester of current pregnancy; cardiovascular diseases; maternal age 18–35 years | IADPSG criteria, at 24–28 weeks' gestation. | FPG, TC, HDL‐C, LDL‐C, TG, TG/HDL‐C ratio, LDL/HDL ratio, TyG index (TG glucose index) | Age, family history of diabetes, 1st trimester BMI |
| Syngelaki 2011, UK | Prospective | Singleton pregnancies at 11–13 weeks' gestation n = 45,191; included n = 41,577 | Not reported | Singleton pregnancies with live foetus and crown rump length of 45–84 mm at 11–13 weeks' gestation, complete data. | Pregnancies conceived by intrauterine insemination incomplete data on pregnancy outcome, pre‐pregnancy type 1 or 2 diabetes, ending in miscarriage or delivery <30 weeks (no screening and diagnosis of GDM) and foetal death <24 weeks. | WHO criteria, 2006 at 24–28 weeks' gestation. | BMI | Maternal age, racial origin, method of conception, cigarette smoking during pregnancy, history of chronic hypertension, history of type 1 or 2 diabetes mellitus (DM), and obstetric history including the outcome of each previous pregnancy |
| Sánchez‐Vera 2007, Spain | Prospective nested case‐control | n = 107; GDM n = 62, non‐GDM n = 45 | July 2001–July 2004 | All women attending obstetric clinic asked to participate; only white women who spoke Spanish fluently included; blood tests performed during routine visits at 15, 24 and 32 weeks | Immigrant women not fluent in Spanish; type 1 and 2 diabetes; multiple pregnancy | American Diabetes Association (ADA), at 24 weeks' gestation | Glucose, TC, TG, weight, BMI | Plasma levels of cholesterol, TG, vitamin E, oestradiol, progesterone, obesity, time of gestation |
| Falcone 2019, Austria | Prospective cohort | n = 574; GDM n = 103, non‐GDM = 471 | January 2016–July 2017 | Not reported | Pre‐existing diabetes | IADPSG criteria at the late second or early third trimester (exact gestational week not reported) | Fasting HbA1c, plasma glucose, insulin, C‐peptide | Age and BMI |
| Sesmilo 2019, Spain | Retrospective analysis | n = 6845; GDM n = 695 (10.2%) | 2008–2018 | Patients with an available FPG in 1st trimester performed in the laboratory under standard conditions, result <110 mg/dl, patients who had complete data for all outcomes | Patients <18 years, pregestational diabetes, multiple pregnancies and/or pregnancies by means of in vitro fertilisation or gonadotropin ovulation induction | NDDG criteria, in 2nd trimester. | FPG | Multivariate logistic model adjusted by maternal age, BMI at the first antenatal visit, previous pregnancies, gestational age, weight gained in pregnancy (transformed into Z‐score) and tobacco use was fitted. |
| Amylidi 2016, Switzerland | Observational retrospective cohort | n = 208; GDM n = 32 (15.2%) | June 2011–November 2012 | Pregnant women attending antenatal clinic with at least one of: BMI ≥ 30 kg/m2, first‐degree family member with diabetes, PCOS, ethnicity (African, Latino, Asian, Pacific Islander), previous pregnancy with GDM or delivery of an infant ≥4.5 kg. | Women with pre‐existing diabetes or a first‐trimester HbA1c ≥ 6.5% (≥48 mmol/mol) | ADA at 24–28 weeks' gestation. | HbA1c, BMI | Not reported |
| Vellamkondu 2017, India | Prospective observational | Women booked between 11 and 14 weeks n = 440; GDM n = 38 | Over 2 years (not stated) | Pregnant women booked between 11 and 14 weeks, singleton viable pregnancy, chose to undergo combined screening for aneuploidy (including nuchal translucency and serum biochemistry) | Not reported | Not reported | BMI | Not reported |
| Wang 2013, China | Prospective | n = 738; PCOS n = 114, controls n = 594 | January 2010–December 2012 | Women diagnosed with PCOS (n = 220) and a matching control group (n = 652); pregnancy confirmed by transvaginal ultrasonography between 6 and 8 weeks' gestation | >40 years, pre‐existing diabetes, cardiomyopathy accompanied by cardiac insufficiency, active hepatitis, uncontrolled hyperthyroidism, active systemic lupus erythematosus, serious hematopathy, malignant tumours, serious trauma, smoking, drug/alcohol use, organic pelvic disease, pregnancy accompanied with acute abdominal disease | At least two values ≥: fasting glucose 5.1 mmol/L, 1 h level 10.0 mmol/L, and 2 h level 8.5 mmol/L. 24–28 weeks' gestation. | BMI | Incidence of pregnancy outcomes according to conception methods (spontaneous conception, IVF‐ET, or ovarian stimulation), age at conception (≤30 years or >30 years), BMI ((<24 kg/m2 (lean) or ≥24 kg/m2 (overweight/obesity)), glucose tolerance state (NGT or GDM) |
| Knight‐Agarwal 2016, Australia | Retrospective cohort | Women from a Birthing Outcome System database, 1st antenatal visit ∼12 weeks' gestation n = 14,857 | January 2008–December 2013 | Not reported | Women with missing BMI data and multiple pregnancies were excluded | International Classification of Diseases (ICD)‐10 codes and standard operating procedures developed by the tertiary institution where the study was conducted. | BMI | Maternal age, parity, country of birth, smoking status |
| Collier 2017, UK | Retrospective cohort | Data extracted from the Scottish Morbidity Record 02, >31 years n = 1,891,097; included in analysis (from 2012 subgroup) n = 47,290 | 1 January 1981–31 December 2012 | Not reported | Delivering at home or in non‐NHS hospitals | Coded as GDM or if any of the diagnosis were coded as O244 (ICD10) or 6488 (ICD9) in the SMR02 dataset. | BMI | Maternal BMI, maternal age, parity status, smoking status, maternal SIMD status |
| Savvidou 2010, UK | Nested case‐control study | First trimester maternal samples from 124 women who developed GDM and 248 control subjects who did not (11 + 0–13 + 6 weeks) | Not stated | Not stated‐ All women had phenotypically normal neonates. | Women with pre‐existing diabetes and twin pregnancies were excluded | 1999 WHO criteria, at 24–28 weeks' gestation | BMI, BP, TC, LDL, HDL, non‐fasting TG, | Maternal age, BMI, gestational age at sampling, smoking, ethnicity, parity, conception status, and previous GDM |
| Kansu‐Celik 2019, Turkey | Retrospective cohort | Women at 1st trimester screening between 6 and 14 weeks' gestation; n = 608; GDM n = 69, non‐GDM n = 539 | January 2010–January 2018 | HbA1c levels were measured <14 weeks' gestation | Multiple gestations, clinical evidence or history of any systemic disease or pregestational diabetes (types 1 and 2), hypertension, FPG exceeding 126 mg/dl, 2 h postprandial values exceed 200 mg/dl, HbA1c ≥ 6.5% during any gestational week, a GCT above 200 mg/dl between gestational weeks 24–28 weeks, positive OGTT during first trimester, history of kidney, liver, or thyroid disease. | Carpenter and Coustan criteria, at 24–28 weeks' gestation. | FPG, HbA1c | Not reported |
| Farah 2012, Ireland | Prospective observational | n = 2000; included n = 1935; GDM screening n = 547, GDM n = 70 | July 2008–March 2010 | White European women; singleton pregnancy | Pre‐pregnancy diabetes; maternal age <18 years; unable to give consent | ADA criteria, diagnosed around 28 weeks' gestation | BMI | Not reported |
| Bao 2018, USA | Nested case‐control | n = 321; GDM n = 107, non‐GDM n = 214 | 2009–2013 | 4 race/ethnic groups; maternal age 18–40 years; singleton pregnancy; pre‐pregnancy BMI 19–45 kg/m2 | HIV; major chronic conditions such as pre‐ pregnancy hypertension, pre‐pregnancy diabetes, cancer, psychiatric, renal or autoimmune diseases | ACOG criteria. Diagnosis time point not reported (but excluded women with GDM <26 weeks' gestation) | TC, HDL, TG, LDL | Maternal age, gestational age at blood collection, parity, family history of diabetes, pre‐pregnancy BMI |
| Odsæter 2015, Norway | Prospective RCT post hoc analyses | n = 228; dropped out n = 12, GDM‐WHO n = 55 (24.1%), GDM‐IADPSG n = 35 (15.4%) | February 2995–January 2009 | Pregnant women with PCOS, 18–45 years, singleton pregnancy between 5 and 12 weeks' gestation | ALT >90 IU/l; creatinine >130umol/l; known alcohol abuse, previous DM, fasting plasma/serum glucose >7.0 mmol/l at inclusion, treatment with glucocorticoids or use of drugs known to interfere with metformin | WHO 1999 criteria, at 24–28 weeks' gestation. | HbA1c | GDM 1st trimester and GDM throughout pregnancy: HbA1c, age and BMI at inclusion, GDM in previous pregnancy, using metformin at conception/early pregnancy pre‐eclampsia: HbA1c, age and BMI at inclusion, using metformin at conception or during pregnancy, GDM‐WHO in 1st trimester, nulliparity, smoking in 1st trimester, pre‐eclampsia in previous pregnancy, pre‐gestational HTN birth weight: HbA1c, age and BMI at inclusion, using metformin at conception or during pregnancy, GDM‐WHO in 1st trimester, nulliparity, smoking in 1st trimester |
| Yang 2019, Australia | Retrospective cohort | Singleton deliveries n = 35,099 (GDM data n = 24,161 (70% retained); GDM n = 2126 (8.8%), non‐GDM n = 22,034 (91.2%) | 2009–2015 | ACT residents, singleton birth, pregnancy duration of between 24 and 43 weeks | Missing maternal height or weight | Not reported (some self‐reported) | 1st antenatal visit BMI | Maternal age, parity, smoking in pregnancy, Aboriginal and TSI status, socio‐economic indexes for areas |
| Sreedevi 2012, India | Observational study (unclear if prospective or retrospective) | n = 250; GDM n = 40, non‐GDM n = 210 | Not reported | Women who registered between 7 and 10 weeks' gestation, regular antenatal check‐up and complete records of antenatal and intranatal periods | Not reported | Not reported | First trimester BMI | Not reported |
| Zheng 2019, China | Prospective cohort | Cohort 1 n = 566; PCOS n = 242, controls n = 324 | Cohort 1 January 2013–December 2015. | 8–15 weeks' gestation; singleton pregnancy; maternal age 18–45 years; history of PCOS (or age and pre‐pregnancy BMI matched controls) | Pre‐existing disease (diabetes, hypertension, liver, kidney, thyroid or cardiovascular disease) | ADA criteria, at 24–28 weeks' gestation. | PCOS, normal BMI <25 and overweight/obese BMI ≥ 25 | Not reported |
| Cohort 2 n = 18,106; PCOS n = 877, controls n = 17,229 | Cohort 2 February 2016–December 2017 | |||||||
| Sánchez‐García 2020, USA | Prospective observational | n = 164; GDM n = 29 (17.7%), non‐GDM n = 135 (82.3%) | November 2017–October 2019 | Maternal age 18–35 years; in 1st trimester of pregnancy (<14 weeks according to last menstrual period) | Maternal age <18 years, taking any medications or had any illness that could impair insulin secretion/action (e.g., prediabetes, types 1 and 2 diabetes, PCOS Rotterdam criteria [53]); multifetal pregnancy; previous GDM or pre‐eclampsia | IADPSG criteria, at 24–28 weeks' gestation. | Triglycerides, BMI | BMI, parity, family history, diastolic blood pressure |
| Hashemi‐Nazari 2020, Iran | Retrospective cohort | n = 1010; analysed n = 1009; GDM n = 80, non‐GDM n = 929 | 2015–2016 | Pregnant women referred to 10 health centres. A certain number of pregnant women | Not reported | ADA criteria, at 24–28 weeks' gestation. | BMI | Age, parity, family history of T2DM, abortion |
| Wani 2020, Saudi Arabia | Longitudinal prospective cohort | n = 498; GDM n = 123 (24.7%) | Not reported | Normal pregnant Saudi women; age 18–35 years; early pregnancy (<15 weeks' gestation); singleton pregnancy | Known previous multiple pregnancy; history of diabetes or chronic disease for example, renal or liver disease | IADPSG criteria, at 27 weeks' gestation | WC, fasting glucose, HDL‐C, TG, SBP, DBP, MetS | Age, BMI, parity |
| Berggren 2017, USA | Prospective observational | n = 300; analysed n = 250; GDM n = 72, non‐GDM n = 178 | June 2012–June 2013 | Maternal age ≥16 years; singleton pregnancy; gestational age 11–14 weeks; no known type 2 diabetes; planned care and delivery at study site; English proficiency | Known type 2 diabetes | Carpenter and Coustan criteria, at 22 0/7 to 33 6/7 weeks of gestation. | HbA1c, SHBG, BMI | HbA1c, SHBG, race, BMI, history of GDM |
| Grewal 2012, India | Prospective observational | Initial Cohort (12 weeks' gestation) n = 298; GDM n = 24 | July 2006–January 2009 | Non‐diabetic women; registered at antenatal clinic <12 weeks' gestation | History of overt diabetes; impaired fasting glucose or impaired glucose tolerance at initial prenatal visits; history of GDM or preeclampsia; taking medications known to affect BGL and insulin levels | Carpenter and Coustan criteria, at 24–28 weeks' gestation. | Early pregnancy plasma glucose, insulin, whole body insulin sensitivity, HOMA‐IR, QUICKI | Age and BMI |
| Repeat Cohort (24 weeks' gestation) n = 215; GDM n = 16 | ||||||||
| Total Cohort n = 298; GDM n = 40 | ||||||||
| Ogonowski 2007, Poland | Retrospective analysis | n = 2425; GDM n = 1414, non‐GDM control n = 1011 | January 1999–December 2005 | Pregnant women with abnormal OGTT, referred to the Outpatient Clinic for Diabetic Pregnant | Pre‐pregnancy diabetes | WHO criteria 1999, at 24–28 weeks' gestation. | Fasting plasma glucose | Not reported |
| Arbib 2019, Israel | Retrospective cohort | First trimester n = 142; GDM n = 42, non‐GDM n = 100 | 1 August 2007–31 December 2014 | Healthy singleton foetus with no known chromosomal or anatomic malformation and known maternal and neonatal short‐term pregnancy outcome | Previous diagnosis of type 1 or 2 diabetes, HbA1C ≥ 6.5%, and/or fasting plasma glucose ≥126 mg/dl; women whose glucose levels had already been tested <24 weeks of pregnancy, or no GDM screening or testing | Carptenter and Coustan criteria, at 24–28 weeks' gestation | HbA1C | Not reported |
| Teede 2011, Australia | Retrospective cohort | Early pregnancy (12–15 weeks' gestation) n = 2880; GDM n = 250, non‐GDM n = 2630 | 2007–June 2008 | All pregnant women (n = 4276) who delivered at Monash Medical Centre | Not reported | ADIPS criteria, at 26–28 weeks' gestation | BMI | Age, increasing BMI, ethnicity, first‐degree family history of diabetes, past history of GDM and/or history of poor obstetric outcome, ethnicity |
| Punnose 2020, India | Retrospective cohort | First trimester (13 6/7 weeks) n = 2275; GDM n = 578, non‐GDM n = 1697 | January 2011–December 2016 | Pregnant women with singleton pregnancies, HbA1c in 1st trimester | Twins, delivery outside the study hospital, HbA1c >6.5%, previous DM, Haemoglobinopathy | IADPSG criteria, at 24–28 weeks' gestation. | HbA1C | Age, BMI, previous GDM, family history of DM, multigravidity, Hb, MCV |
| Berggren 2015, USA | Prospective | Women in pre‐natal care or seeking a first trimester ultrasound n = 250; glucose intolerant n = 72, normoglycemic n = 178 | June 2012–June 2013 | Age ≥16 years; singleton pregnancies at 11 0/7 to 14 6/7 weeks; planned care and delivery at the study site; English language proficiency | No known history of type 2 diabetes mellitus; if GDM screening was performed at an earlier gestational age and GDM was then either diagnosed or treated based on that early screening, or if repeat GDM screening was not performed in the study‐specific gestational age window. | Carpenter and Coustan criteria, at 22–34 weeks' gestation. | HbA1C | SHBG, race, BMI, history of GDM. |
| Li 2016, China | Prospective | Women with PCOS in first pre‐natal visit (<15 weeks' gestation) n = 248; GDM n = 75, non‐GDM n = 173 | 2011–2013 | 18–45 years, diagnosis of PCOS before conception, singleton pregnancy | Pre‐existing chronic diseases including diabetes, hypertension, thyroid, kidney or cardiovascular disease, or multiple pregnancies | ADA criteria, at 24–28 weeks' gestation. | BMI, SBP, DBP, TC, TG, HDL‐C | FPG, non‐HDL‐c, SHBG |
| Riskin‐Mashiah 2010, Israel | Retrospective | n = 4876; GDM n = 135 (2.8%), non‐GDM n = 4741 | June 2001–June 2006 | Singleton pregnancy; 1st trimester BMI; 1st trimester fasting plasma glucose level | Pre‐gestational DM; fasting glucose level >105 mg/dl; delivery at <24 weeks' gestation | Carpenter and Coustan criteria, at 24–28 weeks' gestation. | BMI, fasting glucose | Fasting glucose level, BMI, maternal age, parity |
| Raja 2012, UK | Retrospective | n = 27,668; BMI<30 kg/m2; n = 20,735, BMI>30 kg/m2; n = 3897 | January 2002–December 2007 | Delivering at Northwick Park Hospital, Harrow; delivery date between 1 January 2002 and 31 December 2007 | Lack of data on weight/height | Not reported (hospital database) | BMI | Maternal age, ethnicity, parity, cigarette smoking |
| Gabbay‐Benziv 2015, USA | Prospective cohort | n = 927; GDM n = 63 (6.8%), non‐GDM n = 861 | 2007–2010 | Baltimore metropolitan area; singleton intrauterine pregnancy between 11 and 14 weeks' gestation; prenatal care and subsequent GDM screening at study centre | Strong evidence for pre‐GDM, and missing outcomes | Carpenter and Coustan criteria, at 24–28 weeks' gestation. | BMI, BP | Maternal age, ethnicity, prior GDM, first trimester BMI, SBP |
| Basraon 2016, USA | Prospective cohort | n = 2300; GDM n = 80 (3.5%), non‐GDM n = 2220 | 2003–2008 | Singleton pregnancy; 9–16 weeks' gestation; nulliparous women; no history of pre‐gestational hypertension, proteinuria, diabetes or other medical problems; substance abuse; foetal abnormalities; uterine bleeding; in‐vitro fertilisation | No data of WHR and BMI | GDM diagnosis at 26 weeks' gestation as per the guideline of each centre | BMI, WHR, insulin resistance | Maternal age, education, ethnicity, weeks of gestation at enrolment, alcohol, smoking status |
| Alptehkin 2016, Turkey | Prospective observational | n = 227; GDM n = 20 (8.8%), non‐GDM n = 207 | December 2014–May 2015 | Singleton pregnancy; 7–14 weeks' gestation | Previous type:1 or 2 diabetes, with FPG >95 mg/dl, multiple pregnancies, untreated endocrine disturbances, chronic hypertension, preeclampsia, or medication that affected fasting glucose or insulin levels | Carpenter and Coustan criteria, at 24–28 weeks' gestation. | HOMA‐IR, BMI | BMI, WHR, parity, weight gain during pregnancy, HOMA‐IR |
| Li 2019, China | Retrospective | n = 2112; GDM n = 224 (10.6%), non‐GDM n = 1888 | January 2016–June 2017 | First prenatal visit during 9–13 + 6 weeks' gestation; regular prenatal services; delivered in third affiliated hospital of Sun Yat‐Sen University, Guangzhou, China | Diagnosed pre‐gestational diabetes | IADPSG criteria, at 24–28 weeks' gestation. | FPG | Pre‐pregnancy BMI, first‐trimester FPG, maternal age, parity |
| Wolfe 1991, USA | Prospective | n = 6270 | 30 month period, year not reported | Consecutively delivered of infants at Hutzel Hospital; antepartum and intrapartum records were available | Not reported | Not reported | BMI, maternal weight | Not reported |
| Nanda 2011, UK | Prospective, case‐control | n = 11,464; GDM n = 297 (2.6%), non‐GDM n = 11,167 | March 2006–August 2009 | Women who attended first antenatal visit 11–13 weeks' gestation; singleton pregnancy; delivered phenotypically normal neonate ≥30 weeks' gestation | Pre‐pregnancy type 1 or 2 diabetes; termination, miscarriage or delivery <30 weeks' | WHO criteria 2006, at 24–28 weeks' gestation. | BMI | Maternal age, race, family history of diabetes, parity, cigarette smoking, conception |
| Kumru 2016, Turkey | Prospective cohort | n = 333; GDM n = 38, non‐GDM n = 295 | January 2011–January 2013 | Provided blood samples at 6–13 ± 6 weeks' gestation; completed prenatal care; delivered a live, term infant at institution | Multiple pregnancies; obesity (BMI > 30 kg/m2); history of hypertension; type 1/2 diabetes or glucose intolerance pre‐pregnancy; GDM; preeclampsia; intrauterine 2nd or 3rd trimester pregnancy loss; first‐ or second‐degree relative with diabetes; 1st, 2nd, 3rd trimester losses during follow up; foetal anomaly; did not complete pre‐natal care or deliver at hospital | Carpenter and Coustan criteria, at 24–28 weeks' gestation. | BMIs, MAPs, FBG, insulin, HbA1c, HOMA, TC, LDL‐C, and TG | Maternal age, 1st trimester BMI, MAP |
| Hancerliogullari 2020, Turkey | Prospective cohort | n = 525; GDM n = 49 (9%), non‐GDM n = 476 (91%) | August 2018–November 2018 | Low‐risk pregnant women at 11–14 weeks' gestation. | Maternal age <18 years or >45 years, multiple pregnancies, women with known hypertension, kidney, liver, thyroid gland and other endocrine diseases, those who were diagnosed with pre‐diabetes | Carpenter and Coustan criteria, at 24–28 weeks' gestation. | WC, BMI | Not reported |
| Ozgu‐Erdinc 2019, Turkey | Retrospective cohort study | n = 439; GDM n = 49 (11.2%) | January 2011–January 2012 | Patients who had received antenatal care during 1st trimester | Multiple gestations, medications that affect insulin and glucose levels, hypertension or concomitant systemic disease, pre‐gestational known diabetes (type 1–2) or glucose intolerance and FPG levels ≥126 mg/dl. Four women were excluded as lost to follow‐up | ACOG criteria, at 24–28 weeks' gestation. | FPG | FPG, insulin ratio, HOMA‐IR, HOMA‐b indices, QUICKI |
| Gao 2020, China | Prospective cohort | Training dataset n = 12,887; GDM n = 979 (7.6%). Test dataset n = 6444; GDM n = 506 (7.9%) | October 2010–August 2012 | 19,331 pregnant women registered for antenatal care and two‐step GDM screening. Dataset was randomly divided into two using a computer‐generated random number: The training dataset and the test dataset, with the ratio of sample size of 2:1. The training dataset was used to develop the risk score and the test dataset was used to validate. | History of type 1 or 2 diabetes before pregnancy, 936 who registered and attended their first antenatal care in more than the 15th gestational week, 1163 women who did not undergo GCT, and 851 women who had a positive GCT but did not undergo OGTT. | Changed from WHO 1999 criteria to IADPSG criteria in 2010, at 24–28 weeks of gestation. | BMI, SBP, DBP, weight, WC | Not reported |
| Liu 2020, China | Prospective | Singleton pregnancy n = 352; GDM n = 66 (18.8%), non‐GDM n = 286 | October 2018–December 2018 | Singleton pregnancy, followed up prospectively from the first prenatal visit until delivery. | Not a singleton pregnancy; not Han ethnicity; fasting glucose ≥6.1 mmol/L and/or HbA1c >6.5% or diagnosed as diabetes before pregnancy; history of autoimmune disease, or currently use corticosteroids; hyperthyroidism or hypothyroidism; miscarried or induced labour before OGTT at 24–28 weeks; history of liver or renal insufficiency or CRP >10 mg/L; suspected familial hypertriglyceridemia; incomplete records of lipid profiles and/or FPG concentration. | IADPSG/WHO criteria, at 24–28 weeks of gestation. | BMI, TG, HDL‐C, TC | Age, education, physical activity, BMI (at enrolment), parity, family history of diabetes, history of PCOS, CRP, labour method, foetal sex, gestation age and weight gain |
| Meek 2021, UK | Retrospective | Older Cambridge University Hospital | 2004–2008 | n = 17,736 consecutive women with singleton pregnancies, with random plasma glucose at booking | Not reported | UK National Institute for Health and Care Excellence (NICE; 0 min = 5.6 mmol/l; 120 min = 7.8 mmol/l) and the IADPSG, adopted by the WHO; 0 min = 5.1; 60 min = 10.0; 120 min = 8.5 mmol/l, at 28 weeks' gestation. | Glucose | Not reported |
| NHS Foundation Trust cohort, n = 17,736; GDM cases not specified | ||||||||
| Guo 2020, China | Retrospective cohort was used to develop a prediction model which was assessed on a prospective cohort study | Retrospective n = 3956; GDM n = 662, non‐GDM n = 3294 | January 2015–December 2015 | Eligible subjects who underwent 1st‐trimester screening at the International Peace Maternity and Child Care Health Hospital were recruited at 9–13 weeks' gestation | Pre‐existing diabetes (FPG ≥7 mmol/L or HbA1c ≥ 6.5% during the first antenatal care or self‐reported previous diabetes), multifetal pregnancies, missing data | ADA criteria, at 24–28 weeks' gestation. | FPG, HbA1c | Advanced age, high pre‐pregnancy BMI, diabetes in first degree relatives |
| Wang 2016, China | Retrospective cohort | n = 15,194; included n = 5265; GDM n = 1062, non‐GDM n = 4203 | 20 June 2013–30 November 2013 | Singleton pregnancies delivered between 20 June 2013, and 30 November 2013; | Pre‐existing diabetes mellitus (n = 209), multiple births (n = 253), missing data on early pregnancy lipid and fasting glucose concentrations (n = 9467). | China recommendations: When any one value met or exceeded a 0 h glucose level of 5.1 mM, a 1 h glucose level of 10.0 mM, and a 2 h glucose level of 8.5 mM after a diagnostic 75 g OGTT between 24 and 28 weeks' gestation. | Fasting glucose, TC, TG | Age, family history of DM |
| Al‐Shafei 2021, Sudan | Nested case‐control | GDM: 60, non‐GDM:60 | January–November 2017 | Singleton pregnancies who attended the prenatal care clinic of the hospital during early pregnancy (≤14 weeks' gestation). | Pregnant women with any chronic disease (e.g., diabetes or history of GDM, hypertension, renal disease, liver disease, or thyroid disease) and women who were on medication were excluded | IADPSG, at 24–28 weeks' gestation | FBG, BMI | Not reported |
| Zhang 2020, China | Prospective cohort | GDM: 274, non‐GDM:1111 | December 2017–March 2019 | Recruited at 7–12 weeks' gestation | Not reported | IADPSG criteria, at 24–28 weeks' gestation. | FBG, HbA1c, HDL‐C, SBP, DBP, TG, BMI | Age, BMI, and parity |
| Tenenbaum‐Gavish 2020, Israel | Prospective cohort | GDM:20; non‐GDM:185 | October 2014 and March 2016 | Singleton viable gestation when undergoing combined first trimester screening for aneuploidy. Patients with placentation support hormonal treatment for in vitro fertilisation were only included after discontinuing treatment. | Foetal aneuploidies or major foetal anomalies, increased nuchal translucency thickness >3.5 mm or treatment with aspirin prior to enrolment; termination, miscarriage, or foetal death before 24 weeks' gestation, pre‐eclampsia, birthweight <5th percentile for gestational age, delivered <37 weeks' gestation | Carpenter and Costan criteria, at 24–28 weeks' gestation. | BMI, SBP, DBP | Not reported |
| Leng 2015, China | Prospective cohort | GDM: 1378; non‐GDM: 16,430; within 12 weeks of gestation | October 2010–August 2012 | Not reported | Women who did not have GCT at 24–28 weeks' gestation | 1999 WHO criteria, at 24–28 weeks' gestation. | BMI, SBP, DBP | Age, BMI, and parity, Han nationality, SBP, family history of diabetes in first degree family, education, weight gain from pre‐pregnancy to GCT, smoking and drinking habits |
| Schneider 2021, Australia and New Zealand | Prospective analysis | GDM: 184; non‐GDM: 974 | March 2015–December 2017 | Not reported | Not reported | WHO 2013 criteria, classification, at 24–28 weeks' gestation. | MetS | Maternal BMI, age, ethnicity, SEI, pre‐pregnancy fast food intake, pre‐pregnancy fruit intake, smoking status |
In meta‐analysis, the minimum set of confounding variables included were: maternal age for overweight and obesity analyses; maternal age and BMI for fasting plasma glucose (FPG), TG, HbA1c, HDL‐C, and MetS analyses; and maternal age, BMI, ethnicity, and family history of diabetes, for systolic blood pressure analyses.
Quality assessment
Supporting Information (Table S1) presents the risk of bias using the QUIPS tool for each of the 78 included articles. The overall risk of bias was judged as high for 31 studies (39.7%), moderate for 25 studies (32.0%) and low for 22 studies (28.2%). For individual criteria, 33 studies (42.3%) and 31 studies (39.7%), respectively, were graded as high risk for ‘Adjustment for other prognostic factors’ and ‘Statistical analysis and reporting’. One third of the studies reported a diagnosis of GDM using the 2010 International Association of the Diabetes and Pregnancy Study Groups criteria, 50 which was later adopted by the World Health Organization in 2013 51 ; around a fifth of studies used the Carpenter and Coustan criteria, 52 and around a quarter of included studies did not report on the diagnosis criteria, or used criteria from within their own institution.
Narrative review and meta‐analysis
Supporting Information (Figures S1–S7) illustrates the narrative results reporting on mean differences in each metabolic factor between women with and without GDM. Figures 2, 3, 4, 5, 6, 7, 8, 9, 10 present the OR (95% CI) of maternal prognostic metabolic factors in early pregnancy and the likelihood for GDM. The results of the individual factors are summarised below.
Waist circumference (WC)
Six cohort studies assessed WC with sample sizes ranging from 247 to 19,186. 53 , 54 , 55 , 56 , 57 , 58 Overall, women who developed GDM had a larger WC measured in early pregnancy, with a mean difference of 6.20 cm compared to women without GDM (p < 0.0001; Supplementary Figure S1). 56 , 57 , 58 Studies were not pooled in the meta‐analysis as they did not report on OR or RR.
Body mass index (BMI)
Body mass index was derived from recorded medical history data, self‐report, or from a measurement at the first antenatal visit. There were 44 cohort and six nested case‐control studies, with sample sizes ranging from 106 to 132,899 participants. 49 , 53 , 54 , 55 , 56 , 57 , 58 , 59 , 60 , 61 , 62 , 63 , 64 , 65 , 66 , 67 , 68 , 69 , 70 , 71 , 72 , 73 , 74 , 75 , 76 , 77 , 78 , 79 , 80 , 81 , 82 , 83 , 84 , 85 , 86 , 87 , 88 , 89 , 90 , 91 , 92 , 93 , 94 , 95 , 96 , 97 , 98 , 99 , 100 , 101 Overall, the mean BMI was 2.28 kg/m2 higher in women with GDM compared to women without GDM (p < 0.00001; Supplementary Figure S2). 53 , 56 , 57 , 58 , 59 , 60 , 61 , 62 , 63 , 64 , 65 , 66 , 98 , 99 , 100 , 101
Seven cohort and five case‐control studies with continuous BMI data were included in meta‐analyses. 55 , 58 , 61 , 66 , 67 , 68 , 69 , 70 , 71 , 72 , 98 , 99 For every unit increase in BMI, there was a slight increase in odds for GDM in unadjusted analysis (OR 1.08, 95% CI 1.03–1.13, k = 6; Figure 2A) and analyses adjusted for age, as a key criterion, and up to another 10 confounders (aOR 1.11, 95% CI 1.07–1.14, k = 5; Figure 2B). There was clear heterogeneity across the studies (I 2 ≥ 87%, P het < 0.00001 for both).
FIGURE 2 Meta‐analysis of early pregnancy body mass index (BMI) and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs) for (A) unadjusted and (B) adjusted for maternal age, analyses. For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
Fourteen studies reported on an overweight BMI (>25–<30 kg/m2), 49 , 54 , 59 , 68 , 78 , 79 , 80 , 81 , 83 , 84 , 86 , 87 , 89 , 91 demonstrating a 2‐3 fold increased odds for GDM in unadjusted analyses (OR 2.75; 95% CI 2.02–3.74, k = 6; Figure 3A) and analyses adjusted for age, and up to four other confounders (OR 2.17; 95% CI 1.89–2.50, k = 12; Figure 3B). There was high statistical heterogeneity (I 2 ≥ 73%, P het ≤ 0.002 for both). For the 13 studies including women with obesity (BMI > 30 kg/m2), 24 , 49 , 54 , 59 , 78 , 81 , 83 , 86 , 87 , 89 , 91 , 93 , 94 an obese BMI was associated with a 4‐fold increased odds of GDM (unadjusted OR 4.45; 95% CI 2.77–7.15, k = 8, Figure 4A; adjusted OR 4.34; 95% CI 2.79–6.74, k = 9, Figure 4B), with high statistical heterogeneity (I 2 ≥ 90%, P het < 0.00001 for both).
FIGURE 3 Meta‐analysis of early pregnancy overweight and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs) for (A) unadjusted and (B) adjusted for maternal age, analyses. For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
FIGURE 4 Meta‐analysis of early pregnancy obesity and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs) for (A) unadjusted analysis and (B) adjusted for maternal age. For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
Blood pressure
Ten cohort and two case‐control studies provided data on systolic (SBP), diastolic (DBP), and mean arterial blood pressure with sample sizes ranging from 205 to 17,808 participants. 24 , 53 , 58 , 64 , 66 , 69 , 85 , 99 , 100 , 101 , 102 , 103 Women with GDM had 3.15 mmHg higher mean SBP (p < 00001; Supplementary File 2) 53 , 58 , 64 , 66 , 99 , 100 , 101 , 102 and 1.78 mmHg higher mean DBP (p < 00001; Supplementary Figure S3) 53 , 58 , 64 , 66 , 99 , 100 , 101 , 102 compared to women without GDM.
Raised blood pressure (SBP > 130 mmHg or DBP > 85 mmHg) 24 , 53 or raised SBP 76 , 106 was associated with increased odds for GDM (OR 2.25 95% CI 1.34–3.81, k = 2, adjusted for age, BMI, and up to another seven confounders, Figure 5A; aOR 1.03, 95% CI 1.02–1.04, k = 2, adjusted for age, BMI, family history of diabetes, plus eight confounders, Figure 5B). 69 , 99 There was no statistical heterogeneity between studies for either analysis (both I 2 = 0%, P het > 0.1).
FIGURE 5 Meta‐analysis of blood pressure during early pregnancy and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs) for (A) raised blood pressure (systolic blood pressure >130 mm Hg or diastolic blood pressure >85 mm Hg) and (B) systolic blood pressure; adjusted for maternal age, BMI, family history, and ethnicity. For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
Fasting plasma glucose
Seventeen cohort, three nested case‐control and two retrospective analyses provided data on FPG. 24 , 48 , 53 , 60 , 61 , 62 , 65 , 72 , 73 , 85 , 97 , 98 , 101 , 102 , 104 , 105 , 106 , 107 , 108 , 109 , 110 , 111 Sample sizes ranged from 106 to 17,736 participants. Overall, women with GDM had a mean 0.41 mmol/L higher FPG during early pregnancy compared to women without GDM (p < 00,001; Supplementary Figure S4). 48 , 53 , 60 , 61 , 65 , 101 , 102 , 106 , 107 , 111 Nine studies comprising eight unique samples were included in the meta‐analysis. 53 , 60 , 62 , 72 , 73 , 97 , 104 , 105 Increased FPG in early pregnancy was associated with a higher odds for GDM (unadjusted OR 2.04; 95%CI 1.37–3.04, k = 6, Figure 6A; adjusted for age, BMI, and up to seven other confounders, OR 1.92; 95% CI 1.39–2.64, k = 7, Figure 6B).
FIGURE 6 Meta‐analysis of early pregnancy fasting plasma glucose and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs) for (A) unadjusted and (B) adjusted for maternal age and BMI, analyses. For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
Glycosylated haemoglobin (HbA1c)
Eight cohort, one case‐control, and one randomised controlled trial measured HbA1c in blood samples collected at the first antennal visit. 60 , 61 , 93 , 101 , 106 , 112 , 113 , 114 , 115 , 116 Sample sizes ranged from 142 to 2275 participants. Women who developed GDM had 0.20% higher mean HbA1c in early pregnancy compared to women without GDM (p < 0.0001; Supplementary Figure S5). 60 , 61 , 93 , 101 , 106 , 112 , 113 , 114 Three studies were used in the meta‐analysis, 61 , 93 , 101 demonstrating an association between HbA1c and GDM (adjusted OR 3.88; 95% CI 1.30–11.60, k = 3; Figure 7, I 2 = 49%, P het = 0.14).
FIGURE 7 Meta‐analysis of early pregnancy glycosylated haemoglobin and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs), adjusted for maternal body mass index (BMI). For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
Triglycerides
Thirteen cohort and three nested case‐control studies measured fasting TG in early pregnancy. 24 , 48 , 53 , 61 , 63 , 64 , 65 , 66 , 85 , 101 , 107 , 117 , 118 , 119 , 120 , 121 Sample sizes ranged from 107 to 15,194 participants. Women who developed GDM had higher TG measured in early pregnancy compared to women who did not develop GDM (mean difference 0.24 mmol/L, p < 0.00001; Supplementary Figure S6). 48 , 53 , 61 , 64 , 65 , 101 , 107 , 117
Six studies were included in the meta‐analysis. 53 , 61 , 101 , 117 , 118 , 119 Increasing TG was associated with 1.19‐fold increased likelihood for GDM in analyses adjusted for age, BMI and up to another seven confounders (95% CI 0.95–1.48, Figure 8A) with high statistical heterogeneity between studies (I 2 = 94%, P het < 0.00001, k = 4). Triglycerides >1.7 mmol/L was also associated with higher likelihood of GDM (adjusted OR 1.92; 95% CI 1.30–2.85, I 2 = 0%, P het = 0.73, k = 2; Figure 8B).
FIGURE 8 Meta‐analysis of early pregnancy triglycerides (TG) and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs) (A) per one unit increase in TG and (B) TG > 1.7 mmol/l, adjusted for maternal age and body mass index (BMI). For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
High‐density lipoprotein cholesterol (HDL‐C)
Eight cohort and 2 nested case‐control studies reported on fasting HDL‐C in early pregnancy. 53 , 61 , 63 , 66 , 85 , 101 , 117 , 118 , 119 , 120 Sample sizes ranged from 333 to 5218. Women with GDM had slightly lower mean HDL‐C compared to women without GDM (Supplementary File 2). 53 , 61 , 63 , 66 , 101 , 117 On meta‐analysis, 53 , 85 , 118 , 119 there was insufficient evidence to confirm an association between HDL‐C and GDM (aOR 0.57, 95% CI 0.14–2.32, I 2 = 92%, P het = 0.0004, k = 2; Figure 9A), but an HDL‐C of <1.3 mmol/L was associated with higher odds of GDM (aOR 1.27; 95% CI 1.06–1.51, I 2 = 0%, P het = 0.60, k = 2; Figure 9B).
FIGURE 9 Meta‐analysis of early pregnancy high‐density lipoprotein cholesterol (HDL‐C) and odds of gestational diabetes. (A), Values are odds ratios (OR) with 95% confidence intervals (CIs) for one unit increase in HDL‐C adjusted for maternal age and body mass index (BMI). (B), Odds ratio with 95% CI for low HDL‐C (<1.3 mmol/l) adjusted for maternal age. For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
Metabolic syndrome
Three prospective cohort studies with a sample size ranging from 498 to 3126 were pooled in the meta‐analysis. 24 , 25 , 53 Metabolic syndrome in early pregnancy was associated with a higher odds of GDM in unadjusted (OR 2.58, 95% CI 1.97–3.37, I 2 = 0%, P het = 0.51, k = 2; Figure 10A) and analyses adjusted for age, BMI and up to another 7 confounders (aOR 2.52, 95% CI 1.65–3.84, I 2 = 67%, P het = 0.05, k = 3; Figure 10B).
FIGURE 10 Meta‐analysis of early pregnancy metabolic syndrome and odds of gestational diabetes. Values are odds ratios (OR) with 95% confidence intervals (CIs) for (A) unadjusted and (B) adjusted for maternal age, body mass index (BMI) and family history, analyses. For overall effect, p‐value <0.05 was considered significant (Figure not reproduced here; see the original article.)
Heterogeneity
Sensitivity analyses were performed on adjusted analyses for BMI (continuous and categorical), FPG, and TG (Supporting Information, Figures S8–S12). Removing the studies with high risk of bias marginally reduced the likelihood of GDM in obese women but did not alter the OR or statistical heterogeneity for the other metabolic factors examined. Excluding the outlier studies with a different direction of effect estimate, the statistical heterogeneity became insignificant for BMI as a continuous variable, and marginally increased the adjusted odds ratio for the effect of TG on GDM. When exploring heterogeneity among the obese BMI category, separately eliminating each study with a large effect estimate did not change the odds of GDM or statistical heterogeneity; however, when removing the three studies together, odds for GDM was reduced, with a moderate, albeit statistically significant change in heterogeneity. There were insufficient numbers of studies to perform sub‐group analyses according to GDM criteria within any metabolic factor (Supporting information Figure S13).
DISCUSSION
Principal findings
The purpose of this systematic review and meta‐analysis was to examine the association between maternal MetS and its components with GDM, an independent risk factor for future type 2 diabetes and CVD. 6 Women with overweight or obesity had up to a 4‐fold increased risk for GDM, and increasing FPG or having the MetS as a clustering of factors posed up to a 2.5 times higher likelihood for developing GDM. Findings were consistent in adjusted analyses and persisted in sensitivity analyses to reduce heterogeneity.
Strengths and limitations
Strengths of this review include the extensive and thorough literature search to retrieve relevant eligible studies. The intention to investigate prognostic factors is critically different to prediction models which are used to predict the risk of current disease presence and outcome occurrence in individuals, thereby informing clinical diagnosis. Prognostic research may have an important impact on the translation of interventions from research to clinical practice, to inform health policy and improve patient outcomes. Limitations of the literature reviewed include the overall general moderate or high risk of bias of included studies, mainly because of the lack of adjustment for confounding factors or poor methods of reporting of statistical analyses. The criteria used for diagnosing GDM varied across the included studies, and several studies did not specify how the diagnosis was made. Meta‐analyses also have inherent weaknesses in terms of combining heterogeneous data sets. There was high heterogeneity (I 2 > 50%) for the pooled adjusted analyses for BMI as a continuous or categorical variable, and also for glucose. However, removing studies with a high risk of bias did not alter the effect estimates or heterogeneity, suggesting study quality does not appear to contribute to an overestimation of the magnitude of the effect that these risk factors have on risk for GDM. Comparatively, removing studies with a different direction of effect or with a larger than usual effect size, reduced heterogeneity indicating publication biases apparent. We could not evaluate clinical heterogeneity from the included studies. It is acknowledged that maternal age, BMI and ethnicity are risk factors for GDM. Yet although the studies in our review enroled younger and older pregnant women or women across the BMI spectrum, the studies did not specifically recruit women who were either younger or older, or with low or high BMI, thus sub‐groups could not be created. While many studies also included women across different ethnic groups, studies did not always report on the proportion of different ethnicities included, and where they did, they were not sufficiently homogenous across studies to make comparisons. Thus, the effect of age, BMI, or ethnicity, on the strength of the association with GDM could not be determined. Nevertheless, we did find that even after adjusting for age and BMI, the effect of the different MetS risk factors on GDM was similar to unadjusted analyses.
Comparison with other studies
Women with overweight or obesity had a 2‐4‐fold greater likelihood for development of GDM. A recent meta‐analysis using 33 observational studies demonstrated up to a 3.2‐fold increased odds for GDM with increasing pre‐pregnancy BMI category, and a 19% increased risk of GDM per unit of increase in pre‐pregnancy BMI. 122 Our results for early pregnancy overweight or obesity are in line with findings on pre‐pregnancy BMI, albeit, a smaller increase in odds for GDM (8%) per unit increase. Importantly, for our review, we deliberately focussed on early pregnancy BMI, because losing weight before pregnancy does not appear to alter risk for GDM compared to women who are weight stable. 123 , 124 Pregnant women with overweight or obesity have higher FPG, insulin, and TG, compared to normal weight pregnant women. 125 However, several of the individual studies in this review demonstrated that metabolic risk factors increased risk for GDM, independent of BMI. Since weight loss is not recommended during pregnancy, 126 and targeting pre‐conception women with overweight or obesity is likely to be challenging, our findings reinforce the need to identify other important modifiable risk factors for GDM.
An approximate 2‐fold risk for GDM was demonstrated with increasing level of FPG, which persisted in adjusted and sensitivity analyses. Across gestation, glucose levels reduce due to the maternal adaptations of pregnancy and because of the increased glucose utilisation by the foetal‐placental unit. 127 There is also an increase in insulin resistance. 128 These maternal adaptations potentially limit the use of fasting glucose in early pregnancy for early diagnosis of GDM. However, there is data to show that maternal hyperglycaemia before the routine diagnosis of GDM increases the rate of foetal growth 129 and infant adiposity. 130 , 131 Thus whether to diagnose GDM in early pregnancy is an ongoing point of contention. Our results provide some evidence that testing for early FPG may be useful to intervene in women with high glucose to ameliorate the adverse short and long‐term effects of prolonged intrauterine exposure to hyperglycaemia, but the strength of this evidence is insufficient to alter clinical practice or guide timing of early testing. For measurement of HbA1c, a longer‐term measure of glucose control, three studies were included in the meta‐analysis of which one study had a very small OR with large CIs. Thus, whether HbA1c is useful for early screening of future GDM cannot be established from this analysis and requires further investigation.
Increasing fasting TG was associated with a 1.2‐fold increased likelihood for GDM, however from two studies, triglyceride levels >1.7 mmol/L was associated with a 2‐fold increased risk. Increased TG are associated with insulin resistance, 132 which not only drives the process for MetS, 133 but is also an important factor underlying the development of type 2 diabetes and CVD. 134 , 135 , 136 In a recent study of 500 adults in China, TG positively correlated with insulin resistance in participants with normal glucose tolerance, with a negative, independent correlation with beta cell function in individuals with dyslipidaemia. 132 Indeed, a clustering of abnormalities (i.e. metabolic syndrome) which is related to insulin resistance and/or hyperinsulinemia coupled with dyslipidaemia, may be unfavourable to GDM and overall cardiometabolic health. Our systematic review identified only three studies investigating MetS, and pooling of these studies showed a 2.5‐fold higher likelihood for developing GDM. This odds ratio is higher than the individual risk associated with elevated FPG or TG, but lower to that of obesity. While these observations are important and highlight a potentially important relationship between MetS in early pregnancy and risk for GDM, the studies available were few, warranting further investigation.
Recommendations or clinical implications
Overall, our review cannot provide explicit recommendations or implications for practice for women who may benefit early screening and assessment of MetS factors to identify potential risk for GDM. While the effect estimates remained largely unchanged in sensitivity analyses, the overall high heterogeneity could not be sufficiently tested given the available data from the studies. Moreover, sub‐group analyses in populations at higher risk of GDM, such as older maternal age, higher BMI, and women of minority ethnicities, could not be undertaken. The indication that MetS as a cluster of risk factors demonstrated a doubled risk for GDM, warrants further exploration, both in women with or without obesity.
CONCLUSION
The meta‐analysis provides some evidence that early pregnancy assessment of FPG or the MetS, as a clustering of factors, offers a potential opportunity to detect and treat individual risk factors as an important approach towards GDM prevention. Women with overweight or obesity in pregnancy are also at risk for GDM, however weight loss in pregnancy is not recommended. Given the overall number and quality of studies included, there is a need for further, larger, and higher quality studies to corroborate these results.
CONFLICT OF INTEREST
None to declare.
ETHICS STATEMENT
Ethics approval is not applicable because this study is based exclusively on published literature.
AUTHOR CONTRIBUTIONS
Nahal Habibi: Methodology, Formal analysis, Data Curation, Investigation, Writing ‐ Original Draft, Writing ‐ Review & Editing. Aya Mousa: Data Curation, Investigation, Writing ‐ Review & Editing, Supervision; Chau Thien Tay: Data Curation, Investigation, Writing ‐ Review & Editing. Mahnaz Bahri Khomami: Data Curation, Investigation, Writing ‐ Review & Editing. Rhiannon K. Patten: Data Curation, Investigation, Writing ‐ Review & Editing. Prabha H. Andraweera: Data Curation, Investigation, Writing ‐ Review & Editing. Molla Wassie: Data Curation, Investigation, Writing ‐ Review & Editing. Jared Vandersluys: Data Curation, Investigation, Writing ‐ Review & Editing. Ali Aflatounian: Data Curation, Investigation, Writing ‐ Review & Editing. Tina Bianco‐Miotto: Conceptualization, Data Curation, Investigation, Writing ‐ Review & Editing. Shao J. Zhou: Conceptualization, Data Curation, Investigation, Writing ‐ Review & Editing, Supervision. Jessica A. Grieger: Conceptualization, Methodology, Data Curation, Project administration, Funding acquisition, Writing ‐ Review & Editing, Supervision.
PEER REVIEW
The peer review history for this article is available at https://publons.com/publon/10.1002/dmrr.3532.
Supporting information
Acknowledgements
ACKNOWLEDGEMENTSWe greatly acknowledge the guidance from Dr. Shamil Cooray for the development of the search strategy, and Dr. Rui Wang, for statistical support. Nahal Habibi and Jessica A. Grieger have financial support from the National Health and Medical Research Council (NHMRC) Ideas Grant, awarded to Jessica A. Grieger (GNT 2009038). Aya Mousa is supported by a biomedical research fellowship provided by the NHMRC of Australia (GNT 1161871). CTT holds a scholarship from the Centre of Research Excellence in PCOS and Research Training Program Scholarship from the Commonwealth of Australia.Open access publishing facilitated by The University of Adelaide, as part of the Wiley ‐ The University of Adelaide agreement via the Council of Australian University Librarians.
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