Life tables for Down syndrome

Summary Life expectancy in Down syndrome was calculated to 68 years, using data for 1610 Down syndrome liveborn individuals among over 1.5 million consecutive British Columbia livebirths. Overall, although survival is significantly poorer than for the general population, over half of Down syndrome individuals can be expected to survive into their fifties, and 13.5% will still be alive at age 68. The data are presented as a life table, a practical format for the clinician and planner.     

Prenatal diagnosis, pregnancy terminations and prevalence of Down syndrome in Atlanta

BACKGROUND: The impact of prenatal diagnosis on the live birth prevalence of Down syndrome (trisomy 21) has been described. This study examines the prevalence of Down syndrome before (1990-1993) and after inclusion of prenatally diagnosed cases (1994-1999) in a population-based registry of birth defects in metropolitan Atlanta. METHODS: We identified infants and spontaneous fetal deaths with Down syndrome (n = 387), and pregnancies electively terminated after a prenatal diagnosis of Down syndrome (n = 139) from 1990 to 1999 among residents of metropolitan Atlanta from a population-based registry of birth defects, the Metropolitan Atlanta Congenital Defects Program (MACDP). Only diagnoses of full trisomy 21 were included. Denominator information on live births was derived from State of Georgia birth certificate data. We compared the prevalence of Down syndrome by calendar period (1990-1993, 1994-1999), maternal age (<35 years, 35+ years), and race/ethnicity (White, Black, other), using chi-square and Fisher's exact tests. RESULTS: During the period when case ascertainment was based only on hospitals (1990-1993), the prevalence of Down syndrome was 8.4 per 10,000 live births when pregnancy terminations were excluded and 8.8 per 10,000 when terminations were included. When case ascertainment also included perinatal offices (1994-1999), the prevalence of Down syndrome was 10.1 per 10,000 when terminations were excluded and 15.3 when terminations were included. During 1990-1993, the prevalence of Down syndrome was 24.7 per 10,000 among offspring to women 35+ years of age compared to 6.8 per 10,000 among offspring to women <35 years of age (rate ratio [RR] = 3.65, 95% confidence interval [CI] = 2.53-5.28). During 1994-1999, the prevalence of Down syndrome was 55.3 per 10,000 among offspring to women 35+ years compared to 8.5 per 10,000 among offspring to women <35 years (RR = 6.55, 95% CI = 5.36-7.99). There was no statistically significant variation in the prevalence of Down syndrome by race/ethnicity within maternal age and period of birth strata. During 1994-1999, the proportion of cases that were electively terminated was greater for women 35+ years compared to women <35 years (RR = 5.10, 95% CI = 3.14-8.28), and lower for Blacks compared to Whites among women 35+ years of age (RR = 0.33, 95% CI = 0.16-0.66). CONCLUSIONS: In recent years, perinatal offices have become an important source of cases of Down syndrome for MACDP, contributing at least 34% of cases among pregnancies in women 35+ years of age. Variation in the prevalence of Down syndrome by race/ethnicity, before or after inclusion of cases ascertained from perinatal offices, was not statistically significant. Among Down syndrome pregnancies in mothers 35+ years we found a lower proportion of elective termination among Black women compared to White women. We suggest that future reports on the prevalence of Down syndrome by race/ethnicity take into account possible variations in the frequency of prenatal diagnosis or elective termination by race/ethnicity.     

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.     

Maternal cigarette smoking, Down syndrome in live births, and infant race.

Previous studies have suggested that maternal smoking is negatively associated with a Down syndrome live birth. We analyzed the data of the U.S. Perinatal Collaborative Study in a search for racial variation in Down syndrome risk factors. There were 22 cases in 25,346 live births to smoking mothers (4/10,780 blacks, 18/13,320 whites, and 0/1,246 other races) and 42/29,130 live births to nonsmoking mothers (24/14,665 blacks, 14/11,694 whites, and 4/2,771 others). The crude overall rates per 1,000 live births were 0.4 in black smokers and 1.6 in black nonsmokers but 1.4 in white smokers and 1.2 in white non-smokers. Adjusted for maternal age, the summary relative risk for a Down syndrome live birth to a smoking mother was 0.2 in blacks (95% interval 0.1-0.7) but 1.2 in whites (95% interval 0.6-2.5). Stratification on variables associated with socioeconomic status or gestational age at time of entry into the study did not alter the racial difference. A comparison of smokers with those who never smoked revealed essentially the same trends. Among all nonsmokers the ratio of the maternal age-adjusted risks for a Down syndrome live birth in whites compared with blacks was 0.7 (95% interval 0.3-1.3), and among all smokers this ratio was 3.6 (95% interval 1.3-9.9). If the results are not attributable to statistical fluctuation or undetected confounding, then differences in the probability of intrauterine survival of the Down syndrome fetus would appear to be one plausible explanation for the difference.     

Mutation rates for unbalanced Robertsonian translocations associated with Down syndrome. Evidence for a temporal change in New York State live births 1968--1977.

The mutation rate for translocation Down syndrome was investigated for New York State live births for each of the years 1968--1977 using data from the New York State Chromosome Registry. The overall rate was 2.5 X 10(-5) per gamete (1.4 X 10(-5) for G/21 and 1.0 X 10(-5) for D/21 rearrangements), about 20% higher than rates previously reported by two other studies. For the first 5-year period, 1968--1972, the rate was 1.8 X 10(-5), and for the second 5-year period, 3.1 X 10(-5); there was an abrupt change in 1973 and 1974 to rates more than twice that in the 3 preceding years. These rates were derived by applying completeness estimates for all cases of Down syndrome, mostly 47,trisomy 21, in the jurisdiction to cases with translocation Down syndrome mutations. If completeness corrections are ignored and only the minimum boundaries of rates are considered, however, the increase in 1973 and 1974 was even greater compared with the previous 3 years. The trends, if not attributable to an undetected artifact, may have been caused by an increased frequency of mutant zygotes and/or enhanced intrauterine survival of mutant translocations.     

Cigarette smoking and Down syndrome.

A matched case-control study of 100 mothers of Down syndrome children, 100 mothers of children with other defects (defect controls), and 100 mothers of children with no defects (normal controls) was carried out. All infants were born in upstate New York in 1980 and 1981. Matching was very close on maternal age for the normal controls but not for the defect controls. The risk ratios for the association of cigarette smoking around the time of conception with Down syndrome was 0.58 (90% confidence interval of 0.34-0.98) in the case-defect control comparison and 0.56 (90% confidence interval of 0.33-0.95) in the case-normal control comparison. Stratification by alcohol ingestion and maternal age did not abolish the negative trend to association. The results are contrary to that of an earlier study of others that found a positive association of older age and trisomy in spontaneous abortions. In fact, among mothers of Down syndrome cases over age 30 in this analysis, the risk ratio was lower than for younger mothers. (For case-normal control comparisons, the value was 0.39 [90% confidence interval of 0.17-0.87]). If not due to chance or confounding, the negative association in our data may be attributable to, among other factors, a selective effect of smoking upon survival or fertilizability of +21 gametes prior to conception or upon survival of +21 conceptuses after fertilization.     

Epidemiology of Down syndrome (Trisomy 21), Hawaii, 1986-97

BACKGROUND: The live birth prevalence of Down syndrome is approximately 10 per 10,000 live births in the United States. Down syndrome prevalence has been reported to change over time and to vary by selected demographic factors. METHODS: Data from a population-based birth defects registry in Hawaii involving 363 Down syndrome cases delivered during 1986-97 were used to calculate overall prevalence and to investigate secular trends and differences by selected demographic factors. RESULTS: The total (live birth, fetal death, and elective termination) prevalence was 14.74 per 10,000 live births and fetal deaths. The unadjusted live birth prevalence was 8.67 per 10,000 live births. The adjusted live birth (live births and proportion of elective terminations expected to have resulted in live births) prevalence was 12.59 per 10,000 live births. No significant secular trends were observed for either total prevalence (P = 0.688) or adjusted live birth prevalence (P = 0.604). The total Down syndrome prevalence per 10,000 live births was highest for Far East Asians (22.01), followed by whites (17.06), Filipinos (15.94), and Pacific Islanders (9.21). Prevalence per 10,000 births was higher in metropolitan Honolulu (18.57) than in the rest of Hawaii (14.15). After adjusting for maternal age, however, the differences within the demographic groups were not statistically significant. CONCLUSIONS: The live birth prevalence of Down syndrome in Hawaii during 1986-97 was lower than reported in the literature. Prevalence did not change significantly over time. Any differences in prevalence by maternal race/ethnicity and place of residence appeared to result from differences in maternal age distribution.     

Anti-inflammatory plasma cytokines in children and adolescents with Down syndrome

Cytokines participate in many physiological processes including the regulation of immune and inflammatory responses. Production of some important cytokines in children with Down syndrome (DS) is depressed or increased. In this study we analysed the selected anti- inflammatory cytokines: interleukin-4 (IL-4), interleukin-10 (IL-10), interleukin-13 (IL-13) in plasma of children and adolescents with DS. The study group consisted of 20 patients with Down syndrome and 33 healthy subjects at the age of 5-17 years. Levels of: IL-4, IL-10 and IL-13 in plasma samples were determined by specific enzyme- linked immunosorbent assay (ELISA) techniques according to manufacturer's instructions. IL-4 was detectable in 25% subjects with Down syndrome and in 28.6% healthy subjects. IL-13 was detectable in 15% patients with Down syndrome and in 15.2% healthy subjects, respectively. IL-10 was detectable in 1 of 20 patients with Down syndrome and in 2 of 33 healthy subjects only. No significant correlations between measurable cytokine levels and age and gender were found. No significant increased concentration of selected anti- inflammatory cytokines were detected.     

Down syndrome in British Columbia, 1952-73: incidence and mean maternal age.

Records of children with Down syndrome (DS) at the BC Health Surveillance Registry were linked to their Birth Registrations to derive maternal ages. Incidence and maternal-age specific rates were calculated for 1952-73. Mean maternal age has declined both for normal and DS children, the latter to a marked degree, so that in 1972-73 80% were born to women under 35 years. Using maternal age of 40 and over as an indication for amniocentesis would only detect 10% of DS children. The crude incidence rate (mean 1.28/1000 livebirths) has not changed appreciably over the study period except for 1969 in which a statistically significant peak occurred. The standarized rate showed an increasing trend but it is not clear whether this was a true biological increase or resulted from better ascertainment.     

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.     

Down syndrome rates and relaxed selection at older maternal ages.

Preferential survival in older mothers of fetuses with Down syndrome has been proposed as contributing to the maternal-age effect of this condition. If correct, this provocative hypothesis, which may be termed "relaxed selection," has major implications for approaches to prevention of Down syndrome live births in older women. Several predictions of this hypothesis are examined here by comparisons of parental ages among various populations. These revealed that: (1) mean maternal age of Down syndrome live births is slightly lower than that of Down syndrome spontaneous fetal deaths; (2) mean maternal age of those with mutant D/21 translocation Down syndrome is about the same as that of controls; (3) the ages of Down syndrome mothers who have Down syndrome live births is slightly lower than ages of Down syndrome mothers who have unaffected live births; and (4) in recent data on 47, +21 cases in which the extra chromosome 21 is of paternal origin, the mean maternal ages are 4-5 years lower than the maternal ages of cases of maternal origin (in contrast to earlier reports). All of these observations are contrary to the hypothesis that relaxed selection contributes significantly to the maternal-age association of Down syndrome. If there is any effect of relaxed selection, it is likely to be very weak and/or act primarily upon abortions that occur before recognition of pregnancy.     

中国高老龄人口两性年龄别生存率及其差异变化

本文选用我国４次全国人口普查资料中分年龄性别人口构成的原始数据经移动平均修匀后分析了两性高龄各年龄队列人口在相邻普查期间的生存率及其差异随龄变化,以及每次普查人口高老龄组年龄别性别比。结果表明,两性生存率随龄迅速下降的趋势进入９０岁以后的高老龄组将变平甚或上升;老年组男性年龄别生存率始终低于女性的现象在进入９０岁以后的高老龄组差异迅速缩小并转而反向扩大。结果预示,尽管男性平均期望寿命低于女性,但并     

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.     

Differences in maternal age-specific rates of Down syndrome between Jews of European origin and of North African or Asian origin.

Rates of Down syndrome in livebirths in West Jerusalem in 1964-1975 were studied in relation to the mother's continent of birth or, if she was born in Israel, to the maternal grandfather's continent of birth. In women of European origin the crude livebirth rate of Down syndrome was 1.3 per 1,000 livebirths. This crude rate and the maternal age-specific rates in this group were very close to those observed in a Swedish study and two studies of white livebirths in the United States. For West Jerusalem women of North African or Asian origin the crude rate was about 2.4 per 1,000 livebirths, and at all maternal ages except the youngest their rates were higher than for women of European origin. The summary adjusted relative risk for a Down syndrome livebirth for all those of North African or Asian origin, compared to those for women of European origin, was about 1.56. If attention is restricted to mothers born outside of Israel, the adjusted relative risk for mothers born in Europe, the Americas or English speaking countries of the British commonwealth compared to those born in North Africa or Asia was 1.97, consistent with a two-fold difference in the likelihood of a Down syndrome livebirth between thes two groups. To our knowledge this is the first report of ethnic differences in maternal age specific rates of Down syndrome that cannot be plausibly explained by differences in ascertainment.     

Recurrence risks for down syndrome

Summary The recurrence risks for Down syndrome due to an inherited translocation are estimated from empirical data in the literature for two maternal age groups: mothers under 30 and mothers 30 and over. These risks were found to be approximately 0.3% and 0.05%, respectively. The probability for two Down syndrome sibs both having an inherited translocation was estimated as about 18.2% for the former age group and 2.7% for the latter. The relative effectiveness in preventing Down syndrome births by karyotyping affected children is discussed.     

An investigation of the epidemiology of neuroblastoma in children under the age of 15 years in England, Scotland and Wales

Neuroblastoma is the third commonest tumour of childhood inthe UK, having an incidence rate of 1 in 10 500. Incidence andmortality rates were calculated for the whole of the UnitedKingdom for a period of at least 10 years. The effects of age,stage and regional health authority at diagnosis, year of birth,year of diagnosis and sex on the incidence and mortality rateswere determined. Incidence was found to vary with age and stageat diagnosis, and there was a significant interaction betweenage and stage. A difference in incidence between the sexes wasalso discovered. Mortality was found to vary with age and stageat diagnosis, athough no interaction was found. The findingthat mortality has fallen in recent years may be an artefactdue to recent records being necessarily incomplete. Survivalstatistics were calculated for the UK and certain European cases,and the effects on survival of age, stage, region at diagnosisand sex were determined. Survival varied with age and stageat diagnosis, region of diagnosis and sex, although it was onlypossible to demonstrate significant differences between certainof the stages. It was impossible to test for any interactionterm by the methods used.     

Demography and life history of Thomas langurs (Presbytis thomasi)

Life history data from wild primate populations are necessary to explain variation in primate social systems and explain differences between primates and other mammals. Here we report life history data from a 12.5-year study on wild Thomas langurs. Mean age at first reproduction was 5.4 years and the sex ratio at birth was even. The mean interbirth interval (IBI) after a surviving infant was 26.8 mo, after nonsurviving infants 17.7 mo, and combined 22.0 mo. Mean annual birth rate of adult females was 0.44, while reaching a peak at 6 years of age and showing no decrease with age. Mortality was highest during the first year of life (48.0% for males and 43.0% for females) and consistently higher for males than females. The oldest female observed during the study was estimated to be 20 years of age, whereas the oldest male disappeared at age 13 years, indicating that males die at a much earlier age than females. A Leslie matrix based on these estimates yielded a growth rate of 1.01, which is comparable to the nonsignificant increase in density indicated by our long-term field data. A comparison with life history data for sympatric frugivorous primates suggests that folivory might be associated with faster life history.     

Hospital Admissions in Children with Down Syndrome: Experience of a Population-Based Cohort Followed from Birth

Objective

Children with Down syndrome, the most common genetic cause of intellectual disability, are prone to multiple and varied health-related problems. This study describes patterns of hospitalisations for children and young people with Down syndrome in Western Australia.

Methods

Birth records were linked to the Western Australian population-based Intellectual Disability database to identify all children born with Down syndrome in Western Australia between 1 January, 1983 and 31 December, 1999. These records were linked to the Hospital Morbidity Data System to provide information on all hospitalisations up to 31 December, 2004. Hospitalisation data, coded using ICD-9CM or ICD-10 (v0.5) were grouped into clinically relevant categories using the primary diagnosis. Rates of hospital admission for all and specific diagnoses were expressed in 1000-person-years at-risk and median age at first admission and length of stay were calculated.

Results

Of the 405 children, 395 had one or more hospital admissions, totalling 3786 admissions for all children and an estimated 39.5 person-years in hospital. On average, children were admitted 9.7 times, with an estimated rate of 757.2 admissions per 1000pyr (95% CI: 680, 843). A quarter of all admissions occurred in the first year of life. The average hospital length of stay was 3.8 days (95% CI: 3.7, 4.1). Upper respiratory tract conditions affected the most children (58.5%) and accounted for 12.1% of all admissions. Other disorders which affected a high percentage of children were ear/hearing conditions (50.6%), disorders of the oral cavity (38.0%) and lower respiratory tract conditions (37.5%). Overall, children with Down syndrome were hospitalised at a rate five times (95% CI = 4.3–6.2) that of the general population.

Conclusion

Children with Down syndrome are at increased risk of morbidity for varied causes underlining the importance of comprehensive and targeted primary care for this group.     

Direct and rapid mass spectral fingerprinting of maternal urine for the detection of Down syndrome pregnancy

Background

The established methods of antenatal screening for Down syndrome are based on immunoassay for a panel of maternal serum biomarkers together with ultrasound measures. Recently, genetic analysis of maternal plasma cell free (cf) DNA has begun to be used but has a number of limitations including excessive turn-around time and cost. We aimed to develop an alternative method based on urinalysis that is simple, affordable and accurate.

Method

101 maternal urine samples sampled at 12–17 weeks gestation were taken from an archival collection of 2567 spot urines collected from women attending a prenatal screening clinic. 18 pregnancies in this set subsequently proved to be Down pregnancies. Samples were either neat urine or diluted between 10 to 1000 fold in dH₂O and subjected to matrix assisted laser desorption ionization (MALDI), time of flight (ToF) mass spectrometry (MS). Data profiles were examined in the region 6,000 to 14,000 m/z. Spectral data was normalised and quantitative characteristics of the profile were compared between Down and controls.

Results

In Down cases there were additional spectral profile peaks at 11,000-12,000 m/z and a corresponding reduction in intensity at 6,000-8,000 m/z. The ratio of the normalised values at these two ranges completely separated the 8 Down syndrome from the 39 controls at 12–14 weeks. Discrimination was poorer at 15–17 weeks where 3 of the 10 Down syndrome cases had values within the normal range.

Conclusions

Direct MALDI ToF mass spectral profiling of maternal urinary has the potential for an affordable, simple, accurate and rapid alternative to current Down syndrome screening protocols.     

Factors affecting duckling survival of Eiders Somateria mollissima in northeast Scotland

Mortality factors affecting Eider ducklings Somateria mollissima and their impact with respect to age were studied on the Ythan estuary, Aberdeenshire, Scotland. Survival from hatching to fledging averaged 10.4% over 13 years; numbers declined steeply during the first three to four weeks and slowly thereafter. Growth of tagged young varied considerably between broods. Mortality was not correlated with numbers of ducklings or adults.
Predation in 1974 averaged 13.6% per day during the first two weeks, and accounted for most mortality. Herring Gulls Larus argentatus were the principal predators. Predation was 2.5 times as high in rainy, windy weather as in fine, calm weather. Weather, primarily mean rainfall and wind speed, during early life accounted for over 90% of all variation in survival during eight of nine years. Predation was considered the proximate factor in most weather-related mortality. High survival in 1971 was not explained by weather. An estimated 25–40% of mortality during the second week of life was from renal coccidiosis Eimeria somateriae. Reproductive output of the Ythan population probably limits the rate of population growth, but numbers of breeding birds seem to be regulated by other factors acting after fledging.