Sentences with phrase «adjusting for maternal»

Greater severity of maternal depressive symptoms independently predicted higher externalizing and internalizing scores at 24 months of age, after adjusting for maternal ethnicity and prenatal smoke exposure (Table 2).

Unstandardized coefficients estimates and standard errors are presented for each step in this pathway, adjusting for maternal education and household income.

Linear regression analyses were conducted to determine the regression coefficients (standardized B) and standardized error for each of the proposed pathways, adjusting for maternal education and annual household income.

As seen in Figure 3, the indirect effect of race / ethnicity on externalizing problems through overinvolved parenting, adjusting for maternal education and income, was significant, with a 95 % CI of −.71 to −.02.

After adjusting for maternal level of education, children whose mothers were depressed watched 23 more minutes of TV per day than children whose mothers were not depressed (95 % confidence interval, 4 - 42 minutes), and children whose mothers were obese watched 26 more minutes of TV than those whose mothers were not obese (95 % confidence interval, 8 - 45 minutes).

Similarly, adjusting for maternal smoking in pregnancy, another factor associated with both poor cognitive function and overweight in offspring (38, 58, 59), did not appear to explain the relation between child cognition and obesity.

Formal tests to determine if the above rates of changes in children's diagnoses varied with mothers» remission status were statistically significant (P =.02), and remained significant after further adjusting for maternal depression severity at baseline, maternal treatment setting, annual household income, and child treatment status during the 3 - month follow - up interval (P =.01).

After adjusting for maternal age, education, race / Hispanic ethnicity, marital status, previous live birth, insurance status before pregnancy, method of delivery and maternal length of hospital stay, late preterm infants (34 - 36 weeks) were significantly less likely to sleep on their backs compared to term infants.

After adjusting for maternal IQ and education, characteristics of the home environment, school district, and number of siblings, the children who were exposed to greater than 5 parts arsenic per billion of household well water (WAs ≥ 5 μg / L) showed reductions in Full Scale, Working Memory, Perceptual Reasoning and Verbal Comprehension scores, losses of 5 - 6 points, considered a significant decline, that may translate to problems in school, according to Gail Wasserman, PhD, professor of Medical Psychology in the Department of Psychiatry at Columbia, and the study's first author.

Even after adjusting for maternal age, the rate of twin births rose 1.6 times between 1971 and 2009, the authors reported.

In this study of a population of relatively high socioeconomic status, we found a positive association between duration of breast feeding and mental development, even after adjusting for maternal age, maternal education, maternal intelligence (Raven score), and smoking at the time of conception.

When analysing performance IQ and verbal IQ separately, the risk for children breast fed for less than three months to have a IQ score below the median value, was not statistically different from the other children when adjusting for maternal Raven score (table6).

Women who disliked breastfeeding in the first week were more likely to experience postpartum depression at 2 months (odds ratio [OR] 1.42, 95 % confidence interval [CI] 1.04 — 1.93) adjusting for maternal age, parity, education, ethnicity, and postnatal WIC participation.

Mean and standard errors of monthly weight gain after adjusting for maternal age; race / ethnicity; education; household income; marital status; parity; postpartum Special Supplemental Nutrition Program for Women, Infants, and Children program participation; prepregnancy body mass index (calculated as weight in kilograms divided by height in meters squared); infant sex; gestational age; birth weight; age at solid food introduction; and sweet drinks consumption.

We adjusted for maternal age, ethnic group, understanding of English, marital or partner status, body mass index in pregnancy, index of multiple deprivation score, parity and gestational age at birth (see appendix 4 on bmj.com for categorisation).

In analyses adjusted for maternal race and ethnic group, age, parity, and medical conditions associated with greater risk, the associations between planned location of delivery and most adverse outcomes and obstetrical procedures remained significant (Table 4).

All the models were adjusted for maternal race or ethnic group, parity, insurance status (for cesarean delivery), extent of prenatal care, maternal age and education, history of cesarean delivery, and a composite of maternal conditions associated with an increased medical risk (chronic hypertension, gestational hypertension, preeclampsia, eclampsia, prepregnancy diabetes, or gestational diabetes).

What is most worrying is that this association was adjusted for maternal age, demographic factors, and underlying obstetric complications and therefore reflects the additional risk of the procedure itself.

Although in this study information on breastfeeding practice was reliant upon maternal recall at 9 months, breastfeeding figures are in agreement with data collected prospectively in the UK Infant Feeding Survey conducted in 2000.32 Likewise, the validity of maternal recall of the circumstances of pregnancy and delivery has been shown to be accurate.33 We were unable to adjust for maternal intention to breastfeed at antenatal booking, a factor shown to be important in previous studies34 as this information was not collected in the survey.

In Horwood's long - range study that followed children from birth to 18 years or the completion of high school, breastfed children were rated as more cooperative and socially better students the longer they were breastfed.17 When drop - out rates were calculated, the rate was higher among children who had been bottle - fed and lowest among those who had been breastfed equal to or longer than eight months, even when data were adjusted for maternal demographics.

We identified 4 additional observational studies20 - 23 that adjusted for maternal intelligence and the HOME - SF score.

We also adjusted for maternal intelligence and the HOME - SF score, as well as numerous other potential confounders, and nevertheless found a substantially stronger association (3.75 points) of ever vs never breastfed with verbal IQ at age 7 years.

Estimates of the risk (odds ratio) of getting a «low» WPPSI - R score at age 5 years among children breast fed for less than 3 months compared to children breast fed for six months or more, adjusted for maternal age, education, smoking, and Raven score

Adjusted for maternal age, parity, maternal occupation, cesarean delivery, and smoking during breastfeeding.

All analyses were adjusted for maternal age, parity, occupation, smoking during the breastfeeding period, and the timing of the 6 - mo interview.

Among the maternal anthropometric (dimension 2) variables, only greater BMI was associated with delayed OL, and this relation remained significant in a model adjusted for maternal age.

Among newborn characteristics (dimension 4), higher birth weight and lower 1 - min Apgar score were associated with delayed OL; birth weight > 3600 g remained a significant risk factor in a model adjusted for maternal age and BMI.

Once the data was adjusted for maternal risk (such as smoking, age, education) the group found that there was an increased risk of fetal death for the women who had reduced numbers of antenatal visits.

However, this study neither adjusted for maternal BMI status (the strongest known predictor of child overweight or obesity) nor considered the parenting behaviors or styles of fathers.

Racial / ethnic minorities as well as those of lower socioeconomic status (SES) experience higher rates of family violence as well as higher rates of asthma37 than their white, higher - SES counterparts.38 - 40 Analyses were therefore adjusted for maternal race / ethnicity and maternal education level.

Second, it adjusts for both maternal and paternal BMI status, which are important potential confounders of any association between parenting style and child BMI status.16 Other strengths include its large scale, nationally representative design, and the recency of the data, enabling firm conclusions to be drawn about parenting and obesity as they relate to today's preschoolers and parents throughout Australia.

Note: 1Maternal reports of partner's alcohol consumption; 2Univariable multinomial logistic regression models; 3Multinomial logistic regression models adjusted for maternal age at delivery, parity, Social economic position, maternal education, maternal smoking during first trimester in pregnancy, housing tenure, income, and maternal depressive symptoms at 32 weeks gestation; CL: childhood limited, AO: adolescent onset, EOP: early onset persistent, the Low conduct problems class was used as the reference group.

The analysis with the TTS was adjusted for maternal depression at 21 months and the analyses with the EAS and Rutter Scale were adjusted for maternal depression at 33 months.

2Models adjusted for maternal age at delivery, parity, social economic position, maternal education, maternal smoking during first trimester in pregnancy, housing tenure, income, and maternal depressive symptoms at 32 weeks gestation.

1Maternal reports of partner's alcohol consumption; Model 1 adjusted for maternal age at delivery, parity, social economic position, maternal education, maternal smoking during first trimester in pregnancy, housing tenure, income, and maternal depressive symptoms at 32 weeks gestation; Model 2 further adjusted for maternal alcohol use at 18 weeks gestation.

Finally, models were also adjusted for maternal depression using the Edinburgh Postnatal Depression Scale (EPDS)[26].

1Maternal reports of partner's alcohol consumption; 2Univariable linear regression models; 3Models adjusted for maternal age at delivery, parity, social economic position, maternal education, maternal smoking during first trimester in pregnancy, housing tenure, income, and maternal depressive symptoms at 32 weeks gestation.

Not exact matches

All models were adjusted for potential confounders, including maternal education, ethnicity, smoking, gestational age, birth weight, siblings, and day care attendance.

We used multivariable logistic - regression models to adjust for potential confounders, including maternal race or ethnic group (non-Hispanic white vs. other), parity (nulliparous vs. multiparous), insurance status (public or none vs. other), extent of prenatal care (≥ 5 visits vs. < 5 visits), advanced maternal age (≥ 35 years vs. < 35 years), maternal education (> 12 years vs. ≤ 12 years), history or no history of cesarean delivery, and a composite marker of conditions that confer increased medical risk.

Statistical methods were used to adjust the findings for a range of maternal factors, including BMI, as well as infant sex, gestational age, birth weight, and age of solid food introduction.

Planned out - of - hospital birth was associated with a higher rate of perinatal death than was planned in - hospital birth (3.9 vs. 1.8 deaths per 1000 deliveries, P = 0.003; odds ratio after adjustment for maternal characteristics and medical conditions, 2.43; 95 % confidence interval [CI], 1.37 to 4.30; adjusted risk difference, 1.52 deaths per 1000 births; 95 % CI, 0.51 to 2.54).

The adjusted odds of the secondary maternal outcomes — namely, maternal morbidity avoided and «normal birth» — were significantly increased for planned births in all three non-obstetric unit settings compared with those planned in obstetric units.

We used multiple regression to estimate the differences in total cost between the settings for birth and to adjust for potential confounders, including maternal age, parity, ethnicity, understanding of English, marital status, BMI, index of multiple deprivation score, parity, and gestational age at birth, which could each be associated with planned place of birth and with adverse outcomes.12 For the generalised linear model on costs, we selected a γ distribution and identity link function in preference to alternative distributional forms and link functions on the basis of its low Akaike's information criterion (AIC) statistfor birth and to adjust for potential confounders, including maternal age, parity, ethnicity, understanding of English, marital status, BMI, index of multiple deprivation score, parity, and gestational age at birth, which could each be associated with planned place of birth and with adverse outcomes.12 For the generalised linear model on costs, we selected a γ distribution and identity link function in preference to alternative distributional forms and link functions on the basis of its low Akaike's information criterion (AIC) statistfor potential confounders, including maternal age, parity, ethnicity, understanding of English, marital status, BMI, index of multiple deprivation score, parity, and gestational age at birth, which could each be associated with planned place of birth and with adverse outcomes.12 For the generalised linear model on costs, we selected a γ distribution and identity link function in preference to alternative distributional forms and link functions on the basis of its low Akaike's information criterion (AIC) statistFor the generalised linear model on costs, we selected a γ distribution and identity link function in preference to alternative distributional forms and link functions on the basis of its low Akaike's information criterion (AIC) statistic.

Adjusted for ward type, socioeconomic status, ethnicity, academic qualifications, maternal age, parity, and lone parent status.

Planned out - of - hospital birth was associated with a higher rate of perinatal death than was planned in - hospital birth (3.9 versus 1.8 deaths per 1,000 deliveries, p = 0.003; OR after adjustment for maternal characteristics and medical conditions, 2.43; 95 % CI: 1.37 to 4.30; adjusted risk difference, 1.52 deaths per 1,000 births; 95 % CI: 0.51 to 2.54).

Results were adjusted for several factors including gestational age, maternal age, ethnic background and socioeconomic status.

Model 1 adjusted for covariates in model 0 plus gestational age and birth weight z score.18 Model 2 adjusted for covariates in model 1 plus child race / ethnicity and maternal age, parity, smoking status, depression at 6 months» post partum, and employment and child care at age 6 months, as well as primary language, annual household income, and parental educational level and marital status.

Results Adjusting for sociodemographics, maternal intelligence, and home environment in linear regression, longer breastfeeding duration was associated with higher Peabody Picture Vocabulary Test score at age 3 years (0.21; 95 % CI, 0.03 - 0.38 points per month breastfed) and with higher intelligence on the Kaufman Brief Intelligence Test at age 7 years (0.35; 0.16 - 0.53 verbal points per month breastfed; and 0.29; 0.05 - 0.54 nonverbal points per month breastfed).

Estimates are adjusted for child age, sex, fetal growth, gestational age, race / ethnicity, and primary language and for maternal age, parity, smoking status, IQ, depression, employment, and child care at 6 months» post partum, as well as for parental education level, annual household income, and Home Observation Measurement of the Environment short form score.

Anderson et al. 8 conducted a meta - analysis (n = 11 observational studies) to examine the impact of breastfeeding on cognitive development after adjusting for socio - economic confounders, including the level of maternal education.