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1 nd analyzed them using an age-stage, two-sex life table.
2 d Centers for Disease Control and Prevention life tables.
3 nd 10-14 years, inclusive) using appropriate life tables.
4 on comparisons of survival models with U.S. life tables.
5 ected with hazard-based modifications to the life tables.
6 d on age and sex alone, was calculated using life tables.
7 pulations at risk with census counts and NIH life tables.
8 mortality was estimated from United Kingdom life tables.
9 opulation and death rates from the Minnesota life tables.
10 and 1996 by means of Kaplan-Meier actuarial life-tables.
11 d-generated expected mortality rates from BC life-tables.
13 sease, stage at diagnosis, and survival), US life tables (all cause mortality), and the medical liter
17 st 2 consecutive study visits) determined by life-table analyses, and at least 10 letter (>/=2 line)
26 inical recurrence rates (intent to treat) by life-table analysis at 24 months were 50% (95% confidenc
29 ion of OPMD caused marked debility, although life-table analysis showed no decrease in life expectanc
38 st, Wilcoxon matched-pairs signed-rank test, life-table analysis, Kaplan-Meier method, and log-rank t
48 Well-known methods to do this, such as the life table and age adjustment, exist for binary nonrecur
49 e and comprehensive actuarial foundation for life table and mortality analysis, it suggests new possi
52 llivan method, which was applied to Eurostat life tables and age-specific prevalence of activity limi
54 er-pregnant female donors was analyzed using life tables and time-varying Cox proportional hazards mo
55 nt-level microsimulation model based on U.S. life-tables and in-trial results was used to estimate li
56 rn between 1878 (earliest year with complete life tables) and 1914 (last birth cohort for which male
57 by the time of expected patient death (1990 life tables) and whose Gleason score was less than 4 in
58 e, diabetes, and cancers were modelled using life tables, and changes in greenhouse gas emissions ass
64 et of Alzheimer's disease was derived from a life table constructed by using age-of-onset distributio
66 er were calculated using incidence rates and life table data obtained from the Surveillance, Epidemio
68 calculated from Berkeley Mortality Database life tables derived from population matched by gender an
70 gery demonstrated less strabismus (29 of 50; life-table estimate, 58.0%) than the older cohort (>/= 4
71 ths of follow-up in 38 pseudophakic infants (life-table estimate, 66.7%) and 42 infants (life-table e
72 (life-table estimate, 66.7%) and 42 infants (life-table estimate, 74.5%) treated with contact lenses
77 mity of genomic alterations, correlates with life-table estimates of the probability of overall survi
78 of pregnancies/100 person-years of use) and life-table estimates of the probability of pregnancy wer
87 ze goals of care for geriatric patients, but life tables fail to account for the great variability in
88 The results provide the first estimate of a life table for a population of ant colonies and the firs
90 2)=0.78) of Ne/N in an empirical data set of life tables for 63 animal and plant species with diverse
93 County, Minnesota, and mortality rates from life tables for the general population, we estimated the
98 fer and 100% IDDM by 32 days post-transfer), life-table (log-rank) analyses revealed that IDDM can be
99 groups was compared by means of Kaplan-Meier life-tables, log-rank test, and multivariate proportiona
101 se and cardiac survival was estimated by the life-table method and compared by the log-rank test.
102 -square analysis; rates were computed by the life-table method and compared using Mantel-Cox log-rank
103 months of follow-up was calculated using the life-table method and was compared across treatment grou
109 ive treatments employed before intervention; life-table methodology on an intent-to-treat basis with
111 bserved survival was calculated by actuarial life table methods for three new node-positive subgroups
112 -specific mortality rates is calculated with life table methods that are among the oldest and most fu
117 ) and overall survival (OS) were analyzed by life-table methods according to clinical and biologic fe
126 n be elucidated via several stage-structured life tables of plant populations manipulated by herbivor
127 idated via several methods: stage-structured life tables of plant populations manipulated by herbivor
128 parison, expected survival was obtained from life tables of the population of British Columbia, Canad
129 om the National Center for Health Statistics life tables on the white population in Minnesota, using
132 ectancy and mortality data were derived from life tables, previous studies, and national databases.
133 pregnancy in these women, we used cumulative life-table probabilities and proportional-hazards analys
137 CD2 expression level (> 75% positivity), the life table relative event rate (RER) was 1.22 for patien
139 and undisturbed conditions were evaluated as Life Table Response Experiment and showed that C. microp
140 raphic theory, we develop a set of transient life table response experiments (LTREs) for decomposing
148 sex, and length of follow-up using modified life table technique and surveillance epidemiology end r
149 scipline of classical demography that brings life table techniques, mortality models, experimental sy
150 ops the "Life-Event Table," an analog of the life table that can analyze occurrence of diverse types
152 relative survival, constructing 252 complete life tables to control for background mortality by age,
154 d Centers for Disease Control and Prevention Life Tables to project age- and cause-specific mortality
155 "baseline" age-specific hazards in the local life tables to reflect the life expectancy associated wi
158 appropriate race-specific and state-specific life tables was up to 2% lower for breast cancer and up
160 as well as moderate hypothermia (p < .01 by life table), without a significant difference between mi
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