Paternal age and Down syndrome.

The frequency of Down syndrome (DS) in infants of older fathers has been examined in two sets of data. The effect of maternal age was controlled by single years of age. Lack of tight control has been an important weakness of other studies on this subject. Data obtained in metropolitan Atlanta by an intensive case-ascertainment program showed no overall excess of DS infants born to older fathers. Nor was there evidence of such an effect in recent birth certificate data made available by the National Center for Health Statistics. The Atlanta data suggest an increased number of DS infants born to older fathers who had children by women less than or equal to 34 years. However, there was a small deficiency of DS infants born to older fathers by women greater than or equal to 35 years. The possibility of a paternal-age effect remains open, but the available data suggest that, if it exists, it is quite small.     

Paternal-age and birth-order effect on the human secondary sex ratio.

Because of conflicting results in previous analyses of possible maternal and paternal effects on the variation in sex ratio at birth, records of United States live births in 1975 were sorted by offspring sex, live birth order (based on maternal parity), parental races, and, unlike prior studies, ungrouped parental ages. Linear regression and logistic analysis showed significant effects of birth order and paternal age on sex ratio in the white race data (1.67 million births; 10,219 different combinations of independent variables). Contrary to previous reported results, the paternal-age effect cannot be ascribed wholly to the high correlation between paternal age and birth order as maternal age, even more highly correlated with birth order, does not account for a significant additional reduction in sex-ratio variation over that accounted for by birth order alone.     

A search for a paternal-age effect upon cases of 47, +21 in which the extra chromosome is of paternal origin

If there is a paternal-age effect for 47, +21, it would appear most likely to be present primarily, if not exclusively, in cases in which the extra chromosome is of paternal origin. To search for such an effect, data were reviewed from seven series reporting at least four cases of 47, +21 of paternal origin. The mean of the paternal age-maternal-age difference of such cases (dp) in each series was compared with the mean of the paternal-age differences of cases in the same series that were of maternal origin (dm). If the difference between these (dp - dm or delta) is greater than zero, then this would imply a positive paternal-age effect among cases of paternal origin, at least compared to those of maternal origin. In the seven series, the values of delta ranged from -2.2 years to +3.4 years, and there was no evidence in these comparisons for any consistent trend. A second analysis controlled for any effect of maternal-age variation upon this difference. Each case of paternal origin was matched with a case of maternal origin in the same series that was of the same maternal age. Of 60 cases of paternal origin, exact matches were found for 38. In these 38, the mean value of the difference in parental ages, dp - dm or delta, was negative, about -1.1 (+/- 5.1 years). The difference was highest for the nine cases of paternal origin in which the extra chromosome resulted from presumptive second-division non-disjunction, -1.8 (+/- 3.8 years).(ABSTRACT TRUNCATED AT 250 WORDS)     

An analysis for temporal variation in Down syndrome births in Ohio, 1970–1979

Our study investigates the epidemiology of Down syndrome (DS) in the state of Ohio during the 1970s. The occurrence of DS births was examined to learn if statistically significant temporal variation was present among these data. Both monthly and annual numbers of DS births, adjusted for changing numbers of live births, were tested for such variation; furthermore, the data were analyzed for cyclic variation by attempting to fit simple trigonometric functions to the data.

Individuals with DS were ascertained using the records of cytogenetics laboratories and birth certificate records. Demographic data such as race, date of birth, and maternal age were collected on these individuals using their birth certificates as the data source. Appropriate parallel live-birth data were obtained from the Ohio Department of Health. The total number of affected individuals ascertained was 1,364, 66.7% of the total estimated population size. The data analysis was restricted to whites only (1,203 individuals) because they represented a more homogeneous sample than the total.

Monthly and annual variation in the numbers of live births was removed by producing single-year maternal-age adjusted numbers of DS births using the total Ohio white live births as the reference population. Analysis of covariance using single-year maternal ages ≤ 16 and ≥ 45 as the covariate was used to analyze the adjusted numbers of DS births for temporal variation.

No significant differences were detected among the annual adjusted numbers of DS births (P = .24), nor were there differences among the monthly adjusted numbers of DS (P = .37). The modes of ascertainment were tested to learn if there were annual or monthly differences in the method of ascertainment. No significant differences were detected for these data (P = .82 and P = .85, respectively). Furthermore, the data were separated into the maternal-age categories < 35 and ≥ 35, and annual and monthly adjusted DS births to these two maternal-age categories were examined for temporal variation. No significant differences were found among these data, P > .10 for all four of the tests. No simple cyclic functions were found to fit either the annual or monthly data.

The Ohio study reported here showed that through the use of a large sample, controlling for variation in the numbers of live births, and the use of detailed statistical tests, no significant temporal variation in the occurrence of DS births existed during the 1970s.

     

Thyroid antibodies as a risk factor for Down syndrome and other trisomies.

To test whether the presence of thyroid antibodies in a parent is a risk factor for meiotic nondisjunction, we measured the levels of thyroid antibodies in serum samples drawn during early pregnancy from 101 gravidas who delivered a child with a trisomy, from 11 gravidas who had had a trisomic child in a previous pregnancy, and from 44 of their husbands. For each case mother, three controls were randomly selected from the same population and matched for age, race, sex of the child, and hospital of birth. Cases and controls came from two longitudinal populations, the Child Health and Development Studies (CHDS) and the national Collaborative Perinatal Project (CPP), together comprising more than 70,000 live births. All cases with both a definite diagnosis of trisomy-Down syndrome (DS) or other-and available serum were included. Overall, there was no association between the presence of thyroid antibodies in a mother and a trisomy in her offspring (odds ratio [OR] = .98, confidence interval [CI] = .54-1.85). The lack of association was seen in all three subgroups (DS only, other trisomies, and DS in a previous pregnancy), in all ethnic groups, and in the age groups of white mothers either less than 30 years of age (OR = .80, CI = .40-1.6) or greater than or equal to 30 years of age (OR = 1.26, CI = .82-1.9). In the CHDS population, case fathers, as compared with control fathers, did not have a higher prevalence of thyroid antibodies.(ABSTRACT TRUNCATED AT 250 WORDS)     

Inverse relationship between age at onset of Huntington disease and paternal age suggests involvement of genetic imprinting.

It is well recognized that age at onset of Huntington disease (HD) is strongly influenced by the sex of the affected parent, and this has lead to suggestions that genetic imprinting or maternal specific factors may play a role in the expression of the disease. This study evaluated maternal and paternal ages, birth order, parental age at onset, and sex of the affected parent and grandparent in 1,764 patients in the National HD Roster by using linear-regression techniques which incorporated a weighted least-squares approach to accommodate the correlation among siblings. It was found that paternal age is negatively associated with age at onset of HD, particularly among subjects who inherit the mutant gene from grandfathers. Apparent associations between age at onset and birth order and between age at onset and maternal age were not significant after adjustment for paternal age. The paternal age effect is strongest among juvenile-onset cases and individuals with anticipation of greater than or equal to 10 years, although it is detectable across the entire age-at-onset distribution. The tendency for older fathers, including those not transmitting the HD gene, to have affected offspring with early-onset disease may be consistent with a gene imprinting mechanism involving DNA methylation. Because paternal age in unaffected fathers is also a significant determinant of age at onset, methylation in this context might involve HD modifier genes or the normal HD allele.     

The paternal-age effect in Apert syndrome is due,in part,to the increased frequency of mutations in sperm

A paternal-age effect and the exclusive paternal origin of mutations have been reported in Apert syndrome (AS). As the incidence of sporadic AS births increases exponentially with paternal age, we hypothesized that the frequency of AS mutations in sperm would also increase. To determine the frequency of two common FGFR2 mutations in AS, we developed allele-specific peptide nucleic acid-PCR assays. Analyzing sperm DNA from 148 men, age 21-80 years, we showed that the number of sperm with mutations increased in the oldest age groups among men who did not have a child with AS. These older men were also more likely to have both mutations in their sperm. However, this age-related increase in mutation frequency was not sufficient to explain the AS-birth frequency. In contrast, the mutation frequency observed in men who were younger and had children with AS was significantly greater. In addition, our data suggest selection for sperm with specific mutations. Therefore, contributing factors to the paternal-age effect may include selection and a higher number of mutant sperm in a subset of men ascertained because they had a child with AS. No age-related increase in the frequency of these mutations was observed in leukocytes. Selection and/or quality-control mechanisms, including DNA repair and apoptosis, may contribute to the cell-type differences in mutation frequency.     

Association of paternal age with prevalence of selected birth defects

BACKGROUND: Unlike maternal age, the effect of paternal age on birth defect prevalence has not been well examined. We used cases from the Texas birth defect registry, born during 1996-2002, to evaluate the association of paternal age with the prevalence of selected structural birth defects. METHODS: Poisson regression was used to calculate prevalence ratios (PRs) and 95% confidence intervals (CIs) associated with paternal age for each birth defect, adjusting for maternal age, race/ethnicity, and parity. RESULTS: Relative to fathers ages 25-29 years, fathers 20-24 years of age were more likely to have offspring with gastroschisis (PR 1.47, 95% CI: 1.12-1.94), and fathers 40+ years old were less likely to have offspring with trisomy 13 (PR 0.40, 95% CI: 0.16-0.96). No association was seen between paternal age and prevalence of anencephaly and encephalocele. A selection bias was observed for the other birth defects in which cases of younger fathers were more often excluded from study. CONCLUSIONS: In studies of birth defect risk and paternal age, the source of information may affect the validity of findings.     

Reexamination of paternal age effect in Down's syndrome

Summary The recent discovery that the extra chromosome in about 30% of cases of 47, trisomy 21 is of paternal origin has revived interest in the possibility of paternal age as a risk factor for a Down syndrome birth, independent of maternal age. Parental age distribution for 611 Down's syndrome 47,+21 cases was studied. The mean paternal age was 0.16 year greater than in the entire population of live births after controlling for maternal age. There was no evidence for a significant paternal age effect at the 0.05 level. For 242 of these Down's syndrome cases, control subjects were selected by rigidly matching in a systematic manner. Paternal age was the variable studied, with maternal age and time and place of birth controlled. There was no statistically significant association between paternal age and Down's syndrome. After adjustment for maternal age, these two studies were not consistent with an increase of paternal age in Down's syndrome.     

Paternal age and the occurrence of birth defects

The association between paternal age and the occurrence of birth defects was studied using data collected in Metropolitan Atlanta. Paternal-age information for babies born with defects was obtained from birth certificates, hospital records, and interviews with mothers; for babies born without defects, the information was obtained from birth certificates. Several statistical techniques were used to evaluate the paternal-age-birth-defects associations for 86 groups of defects. Logistic regression analysis that controlled for maternal age and race indicated that older fathers had a somewhat higher risk for having babies with defects, when all types of defects were combined; an equivalent association for older mothers was not found. Logistic regression analyses also indicated modestly higher risks for older fathers for having babies with ventricular septal defects and atrial septal defects and substantially higher risks for having babies with defects classified in the category chondrodystrophy (largely sporadic achondroplasia) and babies with situs inversus. An association between elevated paternal age and situs inversus has not been reported before; the magnitude of the estimated increased risk for situs inversus was about the same as that found in this study for chondrodystrophy.     

Translocation Down syndrome in Ohio 1970-1981: epidemiologic and cytogenetic factors and mutation rate estimates.

Sixteen hundred eighty-eight Down syndrome live births, including 65 (5.2%) translocations, were ascertained in Ohio between 1970 and 1981. Translocations of known origin were 24.4% maternal, 2.2% paternal, and 73.3% de novo. Translocation subtypes were 14/21 (45.7%), 15/21 (2.9%), 21/21 (40.0%), 21/22 (2.9%), and other (8.5%). Among 14/21 translocations, 33.3% were maternal in origin and 66.7% were de novo, while 100% of 21/21 translocations were de novo. No differences were found when the maternal- and paternal-age distributions of all translocations or various translocation subsets were compared with the live-birth control distributions. However, mean maternal and paternal ages of de novo translocations were significantly lower than that of the live-birth controls. Ohio data showed the average maternal age of de novo D/21 cases to be significantly lower than the control. Ages of both parents of de novo G/21 cases and paternal age of D/21 cases were not different from the control. De novo translocation mutation rate estimates were 0.8 X 10(-5) for 14/21, 1.2 X 10(-5) for 21/21, and 2.2 X 10(-5) overall. Ohio estimates (3.2 X 10(-5) for 1970-1972 and 1.4 X 10(-5) for 1973-1975) did not reflect the increase in mutation rate previously found in New York during 1973-1977.     

An analysis of paternal age and 47,+21 in 35,000 new prenatal cytogenetic diagnosis data from the New York State Chromosome Registry: no significant effect

Summary In 35,680 fetuses of women who had prenatal cytogenetic diagnosis done upon amniotic fluid specimens obtained during 2nd trimester amniocentesis and in whom there was no increased cytogenetic risk except for age, there was no statistically significant evidence for an increase of 47,+21 at any paternal age after adjustment for maternal age. The ratio of observed-to-expected numbers in fathers less than 30 years old was 1.0 and in fathers 40 years or older was 0.9 when compared with numbers derived from maternal-age-specific rates in men 30–39 years old. The ratio was 1.1 for those younger than 34 years when compared with rates in fathers aged 34–39 years old. Only for men 55 years or older was there any, even suggestive, increase. The ratio was roughly 1.5 (9 observed to about 6 expected). This was not statistically significant, and moreover, the increase such as it was, was in men married to women 37–42 years old. Regression analyses using several additive parental age models introducing a parabolic function for paternal age, failed to reveal any paternal age contribution.     

Age paternel: apport des données épidémiologiques et d'AMP

Introduction

Maternal age over 35 years is a well known risk factor in reproduction. This effect of maternal age had been demonstrated on the risk of infertility and the risk of miscarriage on the basis of epidemiological data and ART data, especially AID sources. In contrast, the effect of paternal age has been rarely analysed. The objective of this study was to review the literature analysing the effect of paternal age on the risk of infertility and the risk of miscarriage.

Material and method

Sixteen publications analysing paternal age were selected by a MEDLINE search. Thirteen publications concerned epidemiological data, based on surveys in the general population, surveys in pregnant women, case-control studies, and birth and death certificates. Three publications concerned ART data, based on IVF with ovum donation. In IVF with ovum donation, there is no correlation between paternal age and age of the female gamete donor.

Results

Seven epidemiological studies analysed the effect of paternal age on the risk of infertility. After controlling for maternal age, five studies showed a paternal age effect, and one showed a very weak paternal age effect. The last study did not show any paternal age effect, but only considered men under the age of 33 years. Three studies analysed the effect of paternal age on pregnancy rates in IVF with ovum donation. Only one study showed a paternal age effect. The four studies analysing the effect of paternal age on the risk of miscarriage showed a paternal age effect and two of the three studies based on birth and death certificates showed a paternal age effect on late foetal death (>20 weeks of gestation).

Conclusion

There are concordant data in the literature showing an effect of paternal age on the risk of infertility and the risk of miscarriage. Paternal age over 40 years could therefore be a risk factor in reproduction in the same way as maternal age over 35 years. Moreover, the risk of infertility and the risk of miscarriage could be much higher when both partners are over the age of 35–40 years.     

Independent effects of maternal age and birth order on the incidence of selected congenital malformations

Incidence rates, specific for maternal age and birth order, were calculated for 16 categories of congenital malformations reported on birth certificates from a population of more than 8 million registered, white, single livebirths. With maternal age held constant, none of the malformations showed increasing incidence as birth order increased. Hypospadias, esophageal defects, omphalocele, and Down syndrome showed evidence of decreasing incidence as birth order increased. Some of the other malformation categories showed an excess of 1st births in most age groups, while no relation to birth order was observed in the incidence of other malformations. By contrast, most of the malformations analyzed exhibited increasing incidence as maternal age increased. Especially high rates of several malformations were observed among 1st births to women over age 40.     

Origin of trisomy 21 in Down syndrome cases from a Spanish population registry

We have carried out a population-based study on the origin of the extra chromosome 21 in 38 families with Down syndrome (DS) offspring in El Vallès (Spain). From 1991 to 1994, a higher prevalence of DS (22.7/10000 live births, stillbirths and induced abortions) was found compared to the majority of EUROCAT registries. The distribution of trisomy 21 by origin was 88% maternal (90.6% meiosis I, 6.2% meiosis II, 3.1% maternal mosaicism), 5.6% paternal (50% meiosis I, 50% meiosis II) and 5.6% mitotic. The percentage of parental mosaicism was 2.7%. These percentages are similar to those previously reported. Recombination study revealed a maternal meiosis I genetic map of 32.68 cM (approximately one-half the length of the normal female map). Mean maternal age among non-recombinant cases involving MI errors was significantly lower (31.1 years) than among those cases showing one observable crossover (36.1 years) (P<0.05); this could support the hypothesis that 'achiasmate' chromosomes may be subject to aberrant segregation regardless of maternal age.     

Paternal age and Down syndrome in British Columbia

Among Down syndrome cases born in 1964--1976 reported to the British Columbia Registry for Handicapped Children, the mean parental age was about half a year greater than in the entire population of live births after controlling for maternal age, a difference significant at the .05 level. After adjustment for maternal age, a regression analysis was consistent with an increase of 1.024-fold for each year of paternal age. Among Down syndrome cases in 1952--1963, however, for which ascertainment appears likely to be less complete, there was no evidence for a significant paternal age effect. The reasons for the variation between the two groups investigated here and the heterogeneity in results among studies of other populations are discussed.     

Enhanced Maternal Origin of the 22q11.2 Deletion in Velocardiofacial and DiGeorge Syndromes

Velocardiofacial and DiGeorge syndromes, also known as 22q11.2 deletion syndrome (22q11DS), are congenital-anomaly disorders caused by a de novo hemizygous 22q11.2 deletion mediated by meiotic nonallelic homologous recombination events between low-copy repeats, also known as segmental duplications. Although previous studies exist, each was of small size, and it remains to be determined whether there are parent-of-origin biases for the de novo 22q11.2 deletion. To address this question, we genotyped a total of 389 DNA samples from 22q11DS-affected families. A total of 219 (56%) individuals with 22q11DS had maternal origin and 170 (44%) had paternal origin of the de novo deletion, which represents a statistically significant bias for maternal origin (p = 0.0151). Combined with many smaller, previous studies, 465 (57%) individuals had maternal origin and 345 (43%) had paternal origin, amounting to a ratio of 1.35 or a 35% increase in maternal compared to paternal origin (p = 0.000028). Among 1,892 probands with the de novo 22q11.2 deletion, the average maternal age at time of conception was 29.5, and this is similar to data for the general population in individual countries. Of interest, the female recombination rate in the 22q11.2 region was about 1.6–1.7 times greater than that for males, suggesting that for this region in the genome, enhanced meiotic recombination rates, as well as other as-of-yet undefined 22q11.2-specific features, could be responsible for the observed excess in maternal origin.     

Paternal origin of FGFR2 mutations in sporadic cases of Crouzon syndrome and Pfeiffer syndrome

Crouzon syndrome and Pfeiffer syndrome are both autosomal dominant craniosynostotic disorders that can be caused by mutations in the fibroblast growth factor receptor 2 (FGFR2) gene. To determine the parental origin of these FGFR2 mutations, the amplification refractory mutation system (ARMS) was used. ARMS PCR primers were developed to recognize polymorphisms that could distinguish maternal and paternal alleles. A total of 4,374 bases between introns IIIa and 11 of the FGFR2 gene were sequenced and were assayed by heteroduplex analysis, to identify polymorphisms. Two polymorphisms (1333TA/TATA and 2710 C/T) were found and were used with two previously described polymorphisms, to screen a total of 41 families. Twenty-two of these families were shown to be informative (11 for Crouzon syndrome and 11 for Pfeiffer syndrome). Eleven different mutations in the 22 families were detected by either restriction digest or allele-specific oligonucleotide hybridization of ARMS PCR products. We molecularly proved the origin of these different mutations to be paternal for all informative cases analyzed (P=2. 4x10-7; 95% confidence limits 87%-100%). Advanced paternal age was noted for the fathers of patients with Crouzon syndrome or Pfeiffer syndrome, compared with the fathers of control individuals (34. 50+/-7.65 years vs. 30.45+/-1.28 years, P<.01). Our data on advanced paternal age corroborates and extends previous clinical evidence based on statistical analyses as well as additional reports of advanced paternal age associated with paternal origin of three sporadic mutations causing Apert syndrome (FGFR2) and achondroplasia (FGFR3). Our results suggest that older men either have accumulated or are more susceptible to a variety of germline mutations.     

Grandmaternal age in children with Down syndrome in St. Petersburg

Advanced maternal age is a well-established factor of DS occurrence. However the majority of DS cases are born to young couples. Some studies suggested that the risk for Down syndrome may be related to an aging grandmother. We obtained data on grandmaternal ages in 243 families of DS and 330 families of healthy children born in 1990-1999. The data were analyzed according to two categories of maternal ages, <30 yr and > or =30 yr. We did not find systematic differences in grandparental age distribution between the studied groups. Specifically, in 102 young couples with DS, medians for both maternal and paternal grandmother's age appeared to be equal (26 yr). Similar figures were observed in 284 young controls (27 yr). There was no difference in age distribution between 141 older couples with DS and 104 control couples. Therefore we failed to support the suggestion that advanced age of the DS grandmother is responsible for meiotic disturbance in her daughter. Neither the hypothesis suggesting a significant contribution of parentally transmitted trisomy 21 to DS population rate has been confirmed.     

Risk for Asthma in Offspring of Asthmatic Mothers versus Fathers: A Meta-Analysis

Background

Many human epidemiologic studies demonstrate that maternal asthma confers greater risk of asthma to offspring than does paternal disease. However, a handful have shown the opposite. Given this disparity, a meta-analysis is necessary to determine the veracity and magnitude of the “maternal effect.”

Methodology/Principal Findings

We screened the medical literature from 1966 to 2009 and performed a meta-analysis to compare the effect of maternal asthma vs. paternal asthma on offspring asthma susceptibility. Aggregating data from 33 studies, the odds ratio for asthma in children of asthmatic mothers compared with non-asthmatic mothers was significantly increased at 3.04 (95% confidence interval: 2.59–3.56). The corresponding odds ratio for asthma in children of asthmatic fathers was increased at 2.44 (2.14–2.79). When comparing the odds ratios, maternal asthma conferred greater risk of disease than did paternal asthma (3.04 vs. 2.44, p = 0.037). When analyzing the studies in which asthma was diagnosed by a physician the odds ratios were attenuated and no significant differences were observed (2.85 vs. 2.48, N = 18, p = 0.37). Similarly, no significant differences were observed between maternal and paternal odds ratios when analyzing the studies in which the patient population was 5 years or older (3.15 vs. 2.60, p = 0.14). However, in all cases the trend remained the same, that maternal asthma was a greater risk factor for asthma than paternal.

Conclusions/Significance

The results show that maternal asthma increases offspring disease risk to a greater extent than paternal disease.