ライフサイエンスコーパス: hazard

1 ents that represent a potential human health hazard.

2 nd how supervolcanoes work and address their hazards.

3 e potential particle, chemical and microbial hazards.

4 higher late energy intakes reduced mortality hazards.

5 h 10% increase in saturated fat tripled this hazard (adjusted HR: 3.37, 95% CI 1.34 to 8.43, p=0.009)

6 ansplant was associated with lower mortality hazard after the first year compared with the waitlist i

7 The proportional hazard analysis (intention-to-treat and per-protocol pop

8 ctive process control procedures such as the Hazard Analysis Critical Control Point system by seafood

9 Cox hazard analysis was used to extract the adjusted hazard

10 Cox proportional hazard and Fine and Gray competing risk models were used

11 ng adulthood coincide with greater mortality hazard and greater chances of nonadherence to immunosupp

12 Results were analyzed with Cox proportional hazards and flexible parametric models adjusted for stra

13 experienced somewhat greater well-being, and hazards associated with HCT decreased, reaching levels o

14 Although the hazards associated with iron deficiency anemia (IDA) are

15 le for cognitive risk score had an increased hazard for global cognitive impairment compared with tho

16 The hazard for relapse was lower with lisdexamfetamine than

17 els was associated with significantly higher hazards for mortality, whereas higher late energy intake

18 aims to track the health impacts of climate hazards; health resilience and adaptation; health co-ben

19 T and its metabolites and obesity to develop hazard identification conclusions.

20 on after HTx, but the elevation of mortality hazard in this age range persists in the absence of repo

21 admission, we constructed a Cox proportional hazards model adjusting for age, sex, race, and comorbid

22 constructed a multivariate Cox proportional hazards model in which the impact of each covariate was

23 We first fitted a Cox proportional hazards model to examine the relation of knee SxOA to th

24 A multivariate proportional hazards model was used to determine the association of i

25 ersen-Gill extension to the Cox proportional hazards model while accounting for the competing risk of

26 n rehospitalization using a Cox proportional hazards model, following sequential adjustment for covar

27 or disengagement based on a Cox proportional hazards model, using multiple imputation for missing dat

28 splant-free survival with a Cox proportional hazards model.

29 r analyses and multivariate Cox proportional hazard modeling, adjusted for treatment, patient age, ye

30 We used Cox proportional hazard models to calculate multivariate-adjusted hazard

31 Risks were estimated with Cox proportional hazard models.

32 ing for surveillance within Cox proportional hazard models.

33 mortality was assessed with Cox proportional hazards models adjusted for age, sex, AMD severity, VA,

34 idence intervals (CIs) from Cox proportional hazards models adjusting for baseline prognostic factors

35 ations, and biomarkers into Cox proportional hazards models for each outcome.

36 were tested with the use of Cox proportional hazards models that were adjusted for age, sex, body mas

37 We used Cox proportional hazards models to investigate whether associations of br

38 Cox proportional hazards models were fitted to assess associations of ast

39 Cox proportional hazards models were used to analyze variables associated

40 Cox proportional hazards models were used to compute the associations wit

41 posure were estimated using Cox proportional hazards models, adjusted for potential confounders.

42 fied multivariable-adjusted Cox proportional hazards models, black women and men were more likely to

43 lity was investigated using Cox proportional hazards models.

44 separately, using adjusted Cox proportional hazards models.

45 xamined with time-dependent Cox proportional hazards models.

46 cases) were estimated using Cox proportional hazards models.

47 and linear regression, and Cox proportional hazards models.

48 pilepsy were assessed using Cox proportional hazards models.

49 timated using multivariable Cox proportional hazards models.

50 ident all-cause mortality using proportional hazards models.

51 interruption were associated with increased hazard of CD4 decline and death.

52 We modeled the hazard of CRC using Cox proportional hazards regression,

53 x was associated with a 27% reduction in the hazard of death after LVAD (adjusted hazard ratio, 0.73;

54 (<65 versus >/=65 years) indicated a higher hazard of death for patients with preexcitation >/=65 ye

55 iver-related events, but also with a reduced hazard of diabetes mellitus and possibly of chronic rena

56 and repeatable octreotide, PRRT reduced the hazard of disease progression and death by 79%.

57 Hazard of disease progression or recurrence was signific

58 The hazard of dropout will increase from 41% to 46% national

59 The hazard of graft failure was estimated at each current ag

60 After readmission, the hazard of graft loss remained, but decreased 19% per yea

61 ipants receiving insulin therapy had greater hazard of infection (hazard ratio, 2.18; 95% CI, 1.90-2.

62 The hazard of mortality remained, but decreased 14% per year

63 ease in energy intake from fat increased the hazard of relapse by 56% (adjusted HR 1.56, 95% CI 1.05

64 level viraemia was associated with increased hazards of virological failure (hazard ratio [HR] 2.6, 9

65 Hazard rates of AT across lifetime, age at presentation,

66 We found that pupil hazard rates predicted the classification of sub-second

67 re treatment was associated with an adjusted hazard ratio (aHR) for treatment failure of 20.4 (95% CI

68 r disease-specific survival [(+)transfusion: hazard ratio (HR) 1.19, 95% confidence interval (CI) 1.0

69 did not have a higher risk of breast cancer (hazard ratio (HR) = 0.95, 95% confidence interval (95% C

70 breast cancer among those with AF (adjusted hazard ratio (HR) = 1.19, 95% confidence interval (CI):

71 CHOP) of patients having had PFS events, the hazard ratio (HR) for PFS was 0.73 (90% CI, 0.43 to 1.24

72 ional biopsy was associated with an adjusted hazard ratio (HR) of 3.0 (95% CI, 2-4.5) and, via core n

73 Compared to subjects without diabetes, hazard ratio (HR) of TKR for subjects with diabetes was

74 netics subgroups: in high-risk patients, the hazard ratio (HR) was 0.543 (95% confidence interval [CI

75 of 14.6% (95% CI, 5.7% to 23.5%); P = .014; hazard ratio (HR), 1.76 (95% CI, 1.11 to 2.79).

76 By assigning hazard ratio (HR)-weighted points to these variables, th

77 t [first quintile, referent; second quintile hazard ratio (HR)=1.03 [95% confidence interval (CI): 0.

78 was significantly longer in the BRCA mutant (hazard ratio 0.27, 95% CI 0.16-0.44, p<0.0001) and LOH h

79 elevated LMR was associated with better OS (hazard ratio 0.569, 95% confidence interval: 0.478-0.677

80 n colorectal cancer incidence rate (adjusted hazard ratio 0.57, 95% CI 0.40-0.80 for one visit; 0.51,

81 5 months (1.5-1.7) in the dacarbazine group (hazard ratio 0.62 [95% CI 0.47-0.80]; one-sided p<0.001)

82 d 7.3 months (5.9-8.7) in the placebo group (hazard ratio 0.92 [95% CI 0.76-1.12], p=0.41).

83 e risk difference -1.4%, 95% CI -7.0 to 4.3; hazard ratio 0.96, 0.68-1.35, p=0.81).

84 up and 67% (65-69) for the sequential group (hazard ratio 0.96, 0.88-1.05; p=0.39).

85 n observed BMI and AF (age- and sex-adjusted hazard ratio 1.05 [1.04-1.06] per kg/m(2), P<0.001).

86 cardiovascular disease events (standardised hazard ratio 1.59, 95% CI 1.27-1.98; p<0.0001), a findin

87 compared with those in the lowest quartile (hazard ratio 18.4 [95% CI 9.4-36.1]).

88 mokers had significantly lower risks of BCC (hazard ratio = 0.6; 95% confidence interval = 0.4-0.9) b

89 at menarche, risk of MS was reduced by 13% (hazard ratio = 0.87, 95% confidence interval: 0.79, 0.96

90 an in the antiinflammatory-stable DII group (hazard ratio = 1.32, 95% confidence interval: 1.01, 1.74

91 erval: 1.4, 1.6) and cardiovascular disease (hazard ratio = 1.4, 95% confidence interval: 1.2, 1.6),

92 5 million/mL and all-cause hospitalizations (hazard ratio = 1.5, 95% confidence interval: 1.4, 1.6) a

93 atus was confirmed on multivariate analysis (hazard ratio = 1.694, 95% confidence interval 1.175-2.44

94 -0.9) but significantly higher risks of SCC (hazard ratio = 2.3; 95% confidence interval = 1.5-3.6).

95 harge was associated with improved survival (hazard ratio [95% CI], 0.96 [0.94-0.98]), with similar f

96 with a 28% higher risk of dementia (adjusted hazard ratio [aHR], 1.28; 95% CI, 1.13-1.46) adjusted fo

97 in persons with moderate fibrosis (adjusted hazard ratio [aHR], 1.42 [95% confidence interval {CI},

98 r patients with metastatic disease (adjusted hazard ratio [AHR], 2.3; 95% CI, 1.0 to 5.1; P = .04) an

99 ardiovascular events (multivariable adjusted hazard ratio [HR(adj)]=0.75, 95% CI 0.66-0.85, p<0.0001)

100 hs [95% CI 2.8-4.2] vs 1.8 months [1.5-2.8]; hazard ratio [HR] 0.67, 95% CI 0.53-0.84, one-sided p=0.

101 ths vs 30 months in the Rd group; stratified hazard ratio [HR] 0.712, 96% CI 0.56-0.906; one-sided p

102 [95% CI 11.8-15.7] vs 9.6 months [8.6-11.2]; hazard ratio [HR] 0.73 [95% CI 0.62-0.87], p=0.0003).

103 5% CI 2.96-4.47] vs 2.76 months [2.60-2.96]; hazard ratio [HR] 0.757, 95% CI 0.607-0.943; p=0.0118).

104 end point consistently in patients with PAD (hazard ratio [HR] 0.79; 95% confidence interval [CI], 0.

105 There was no difference in overall survival (hazard ratio [HR] 1.04, 95% CI 0.90-1.19; p=0.61).

106 in the chemotherapy plus bevacizumab group (hazard ratio [HR] 1.08, 95% CI 0.91-1.29; p=0.36).

107 ] of 283) than for BUP-NX (163 [57%] of 287; hazard ratio [HR] 1.36, 95% CI 1.10-1.68), most or all o

108 th increased hazards of virological failure (hazard ratio [HR] 2.6, 95% CI 2.5-2.8; p<0.0001) and swi

109 nitive status (subjective cognitive decline: hazard ratio [HR] = 0.57, p < 0.05; mild cognitive impai

110 ARDs) had the highest risk of HBVr (adjusted hazard ratio [HR] = 5.14; 95% confidence interval [CI] =

111 eased incidence of hepatocellular carcinoma (hazard ratio [HR] compared with patients without an SVR,

112 Older age (hazard ratio [HR] per 10 years, 1.64; 95% CI, 1.19-2.27;

113 of 90 people with a Mars1 endotype had died (hazard ratio [HR] vs all other endotypes 1.86 [95% CI 1.

114 f the two-sided 95% CI for the local relapse hazard ratio [HR] was less than 2.03), analysed by inten

115 ion analysis, treatment with either regimen (hazard ratio [HR], 0.43; 95% confidence interval [CI], .

116 oved survival were treatment with sorafenib (hazard ratio [HR], 0.66; 95% confidence interval [CI], 0

117 ons between low IOP and time to reoperation (hazard ratio [HR], 0.73; 95% CI, 0.32-1.68), vision loss

118 icantly improved with PAG treatment overall (hazard ratio [HR], 0.73; 95% CI, 0.53 to 1.00; P = .049)

119 African Canadians (hazard ratio [HR], 0.75; 95% CI: 0.62-0.92]) and patient

120 he 2000-2004 period to the 2009-2012 period (hazard ratio [HR], 0.79; 95% CI, 0.73-0.85).

121 ficant difference in the risk of DFS events (hazard ratio [HR], 1.00; 95% CI, 0.78 to 1.28; P = 1.00)

122 ssociated with higher CSF neutrophil counts (hazard ratio [HR], 1.10 per 10% increase; 95% confidence

123 lically unhealthy non-obese (MUNO) subjects (hazard ratio [HR], 1.29; 95% confidence interval [CI], 1

124 rtality was higher for nonadherent patients (hazard ratio [HR], 1.57; 95% CI, 1.07-2.30; P < .001), a

125 95% CI, 1.06-1.25]; autism spectrum disorder hazard ratio [HR], 2.02 [95% CI, 1.80-2.26]; attention-d

126 nalysis (MVA), pre-existing cardiac disease (hazard ratio [HR], 2.96; 95% CI, 1.07 to 8.21; P = .04)

127 of the composite of all-cause death and MI (hazard ratio [HR]: 0.65; 95% confidence interval [CI]: 0

128 ith reduced risks of >/=30% decline in eGFR (hazard ratio [HR]: 0.77; 95% confidence interval [CI]: 0

129 nsistent at each subsequent landmark (year 1 hazard ratio [HR]: 0.82; 95% confidence interval [CI]: 0

130 ly reduced the risk of MACE by 14% in women (hazard ratio [HR]: 0.86; 95% confidence interval [CI]: 0

131 The adjusted hazard ratio for acute rejection and all-cause mortality

132 The highest quartile hazard ratio for DDKF was 2.47 (95% confidence interval

133 nusinersen group than in the control group (hazard ratio for death or the use of permanent assisted

134 RVD alone (50 months vs. 36 months; adjusted hazard ratio for disease progression or death, 0.65; P<0

135 independently with a higher risk of AF; the hazard ratio for each 1 SD lower SD of normal-to-normal

136 ed weight loss after 1 year was related to a hazard ratio for heart failure of 0.77 (95% confidence i

137 se who received CRT without a defibrillator (hazard ratio for mortality adjusted on propensity score

138 The estimated hazard ratio for overall survival in patients with follo

139 The adjusted hazard ratio for publication was 1.79 (95% confidence in

140 ced AKI Network stage 2 or 3 had an adjusted hazard ratio for the primary composite outcome of 3.52 (

141 estimate (as a continuous variable) showed a hazard ratio of 2.25 (95% confidence interval, 1.70-2.99

142 relatives of patients with AVNRT presented a hazard ratio of at least 3.6 for exhibiting AVNRT compar

143 ate Cox proportional hazards regression, the hazard ratio of HD in the first 30 days was 2.17 (95% CI

144 The hazard ratio of qSOFA score for death was 6.2 (95% CI, 3

145 al replacement therapy interaction (adjusted hazard ratio range, 0.43-0.89; p < 0.001).

146 higher mortality throughout 1-year (adjusted hazard ratio range, 1.30-1.92; p < 0.001), which was att

147 o, 0.29; 95% CI, 0.25 to 0.34; P<0.001); the hazard ratio was 0.21 in patients with nonmetastatic dis

148 red with those aged 18 to 24 years (adjusted hazard ratio, 0-5 years = 0.36; 6-11 = 0.29; 12-17 = 0.4

149 as compared with 535 in the ADT-alone group (hazard ratio, 0.29; 95% CI, 0.25 to 0.34; P<0.001); the

150 earlier-generation fluoroquinolone (adjusted hazard ratio, 0.46 [95% confidence interval, .26-.80]) d

151 months for the placebo or observation group (hazard ratio, 0.48; 95% CI, 0.41 to 0.55).

152 hlorambucil led to significantly better EFS (hazard ratio, 0.54; 95% CI, 0.38 to 0.77).

153 idence than lifestyle modification patients (hazard ratio, 0.54; 95% confidence interval, 0.36-0.82).

154 l nephrectomy had reduced risk of mortality (hazard ratio, 0.55; 95% CI, 0.49 to 0.62).

155 atively similar in the unmatched population (hazard ratio, 0.57; 95% confidence interval, 0.33-0.98;

156 associated with no bystander resuscitation (hazard ratio, 0.62; 95% confidence interval [CI], 0.47 t

157 ed with a lower likelihood of ICU discharge (hazard ratio, 0.65 [0.42-1.00]; p = 0.01), longer deliri

158 in damage, nursing home admission, or death (hazard ratio, 0.67; 95% CI, 0.53 to 0.84).

159 ell as a lower risk of death from any cause (hazard ratio, 0.70; 95% CI, 0.50 to 0.99) and a lower ri

160 in the hazard of death after LVAD (adjusted hazard ratio, 0.73; 95% confidence interval, 0.58-0.92;

161 as associated with a significant OS benefit (hazard ratio, 0.77 [95% CI, 0.68 to 0.88]; P < .001).

162 of 158 patients (54%) in the placebo group (hazard ratio, 0.78; 95% CI, 0.57 to 1.07; P=0.12).

163 ion at 5 years relative to capping (adjusted hazard ratio, 0.78; 95% CI, 0.62-0.97; P=0.027).

164 een the 48-hour group and the 24-hour group (hazard ratio, 0.79; 95% CI, 0.54-1.15; P = .22).

165 ndary end point (816 [5.9%] vs. 1013 [7.4%]; hazard ratio, 0.80; 95% CI, 0.73 to 0.88; P<0.001).

166 prednisolone use for exacerbation was found (hazard ratio, 0.82; 95% CI, 0.58-1.17; P = 0.28).

167 h PCI, CABG still showed a survival benefit (hazard ratio, 0.82; 95% confidence interval, 0.75-0.90;

168 262 of 9151 (2.9%) randomized to PCI alone (hazard ratio, 0.84; 95% confidence interval, 0.70-1.01;

169 4 patients [9.8%] vs. 1563 patients [11.3%]; hazard ratio, 0.85; 95% confidence interval [CI], 0.79 t

170 per 100 person-years) in the placebo group (hazard ratio, 0.91; 95% confidence interval [CI], 0.83 t

171 oup and in 356 (9.3%) in the glargine group (hazard ratio, 0.91; 95% confidence interval, 0.78 to 1.0

172 rtality rates compared with whites (adjusted hazard ratio, 0.92; 95% CI, 0.76-1.11 and adjusted hazar

173 ratio, 0.92; 95% CI, 0.76-1.11 and adjusted hazard ratio, 0.92; 95% CI, 0.76-1.12, respectively).

174 interval, 0.94-1.15; P=0.46) or amlodipine (hazard ratio, 0.93; 95% confidence interval, 0.84-1.03;

175 mortality after propensity score adjustment (hazard ratio, 0.94; 95% CI, 0.89-0.99), and the benefici

176 ial effect could extend to 90-day mortality (hazard ratio, 0.95; 95% CI, 0.89-1.00).

177 confidence interval, 1.06-1.24; P=0.001, and hazard ratio, 0.99; 95% confidence interval, 0.92-1.07;

178 al MBF and clinical covariates; and adjusted hazard ratio, 1.03; 95% CI, 0.84-1.27; P=0.8 per unit de

179 alidone, randomization to either lisinopril (hazard ratio, 1.04; 95% confidence interval, 0.94-1.15;

180 ts was similar to standard ICD RPM patients (hazard ratio, 1.06; 95% confidence interval, 0.94-1.19;

181 1-U increase, P<0.001) and incident AF (FTO, hazard ratio, 1.07 [1.02-1.11] per A-allele, P=0.004; BM

182 C transfusion was not associated with death (hazard ratio, 1.07; 95% CI, 0.88-1.30; p = 0.52).

183 idence interval: 1.11, 1.33) and MELD score (hazard ratio, 1.08; 95% confidence interval: 1.06, 1.11)

184 1.11] per A-allele, P=0.004; BMI gene score, hazard ratio, 1.11 [1.05-1.18] per 1-U increase, P<0.001

185 I], -1.5 to 2.8; P=0.007 for noninferiority; hazard ratio, 1.12; 95% CI, 0.79 to 1.58; P=0.53); the u

186 for health status and psychosocial factors (hazard ratio, 1.14; 95% confidence interval, 0.96-1.35),

187 edictor of outcomes in men but not in women (hazard ratio, 1.14; 95% confidence interval, 1.06-1.24;

188 he chronic phase, the effect was attenuated (hazard ratio, 1.16; 95% confidence interval, 1.08-1.25;

189 r adjustment for competing risks, LSN score (hazard ratio, 1.22; 95% confidence interval: 1.11, 1.33)

190 wever, the risk of hospitalization (adjusted hazard ratio, 1.34; 95% confidence interval, 1.11-1.60;

191 xperimental arm (median, 21.8 v 24.5 months; hazard ratio, 1.38; 95% CI, 0.99 to 1.94; P = .06).

192 ed with children without asthma at baseline (hazard ratio, 1.51; 95% confidence interval, 1.08-2.10)

193 fter adjustment for all confounding factors (hazard ratio, 1.69; 95% confidence interval, 1.10-2.61;

194 ndependent prognostic factor for recurrence (hazard ratio, 1.78; P=0.005).

195 , and revascularization after scan (adjusted hazard ratio, 1.79; 95% confidence interval [CI], 1.38-2

196 predicted risk for subsequent MACE (adjusted hazard ratio, 1.90; 95% confidence interval, 1.46-2.48;

197 was the strongest univariable PFS predictor (hazard ratio, 1.97; 95% CI, 1.44 to 2.71; P < .001).

198 ns at a rate >200 beats per minute (adjusted hazard ratio, 15.63; 95% confidence interval, 4.01-60.89

199 highly associated with recurrent stroke/TIA (hazard ratio, 2.0; 95% confidence interval, 1.9-2.1).

200 nce interval, 1.11-1.60; P=0.002) and death (hazard ratio, 2.10; 95% confidence interval, 1.60-2.75;

201 sed mortality at 4 months both in allo-HSCT (hazard ratio, 2.13; 95% confidence interval, 1.45-3.13;

202 P<0.001), and cardiovascular death (adjusted hazard ratio, 2.16; 95% confidence interval, 1.36-3.43;

203 lin therapy had greater hazard of infection (hazard ratio, 2.18; 95% CI, 1.90-2.51) but no increased

204 ry were because of noncardiovascular causes (hazard ratio, 2.32; 95% confidence interval, 1.92-2.81 v

205 creased rate of ILD-specific death (adjusted hazard ratio, 2.3; 95% confidence interval, 1.7-3.0; P <

206 dent prognostic factor for overall survival (hazard ratio, 2.480; 95% confidence interval [CI], 1.386

207 46-2.48; P<0.001), all-cause death (adjusted hazard ratio, 2.96; 95% confidence interval, 2.01-4.36;

208 ior sclera (LD-AS decrease) reference plane (hazard ratio, 3.23; P < 0.01).

209 mab in addition to the chemotherapy regimen (hazard ratio, 3.3; 95% CI, 1.0-14.7; P = .06).

210 -year cumulative event rates, 3.5% vs. 0.9%; hazard ratio, 3.87; 95% CI, 1.78 to 8.42; P<0.001).

211 ling with AS had an exceptionally high risk (hazard ratio, 32.84) but were uncommon (34 siblings from

212 th HF with preserved ejection fraction only (hazard ratio, 5.0; P=0.001).

213 ter adjustment for traditional risk factors (hazard ratio, 5.12; 95% CI, 1.56-16.7; P = .007).

214 4.01-60.89; P<0.0001) and >7 beats (adjusted hazard ratio, 6.26; 95% confidence interval, 2.02-19.41;

215 o those with no increase or increases <0.25 (hazard ratio, 9.766; 95% confidence interval [CI], 4.356

216 red for 77 DCS and 136 BMS patients (12.0%) (hazard ratio: 0.54; 95% confidence interval: 0.41 to 0.7

217 s with DCM, no such difference was observed (hazard ratio: 0.92; 95% CI: 0.73 to 1.16; p = 0.49).

218 ity (p < 0.0005) and 1-year death and/or HF (hazard ratio: 1.27; 95% CI: 1.10 to 1.45; p = 0.001).

219 associated with an increased risk of death (hazard ratio: 2.05; p < 0.0001).

220 ciated with a higher risk of major bleeding (hazard ratio: 2.19; 95% confidence interval: 1.07 to 4.4

221 C <25 mg/dl (2.6%) versus >/=25 mg/dl (0.8%; hazard ratio: 3.40; 95% confidence interval: 1.58 to 7.3

222 proved global longitudinal strain at 1 year (hazard ratio=0.29; P<0.001).

223 d a higher risk of bleeding hospitalization (hazard ratio=1.21; P=0.021) but a similar risk of death,

224 /=5 m/s had greater mortality risk (adjusted hazard ratio=1.86 [1.55-2.54]; P<0.001), even in the sub

225 subgroup of asymptomatic patients (adjusted hazard ratio=2.08 [1.25-3.46]; P=0.005).

226 re, widowhood increased risk for AUD in men (hazard ratio=3.85, 95% CI=2.81-5.28) and women (hazard r

227 ard ratio=3.85, 95% CI=2.81-5.28) and women (hazard ratio=4.10, 95% CI=2.98-5.64).

228 es within 3 months of medication initiation (hazard ratio=6.7, 95% CI=2.0-22.4), with similar results

229 onger activated partial thromboplastin time (hazards ratio, 0.98; p = 0.002) and decreased platelet c

230 to cause clotting compared with 150 mL/min (hazards ratio, 1.00 [0.60-1.69]; p = 0.68).

231 98; p = 0.002) and decreased platelet count (hazards ratio, 1.19; p = 0.03) were associated with a re

232 ing compared with use of heparin strategies (hazards ratio, 1.62; p = 0.003).

233 For SPK transplantation, low (adjusted hazard ration [aHR], 1.55, 95% confidence interval [CI],

234 We estimated hazard ratios (HR) and 95% CIs with multivariate Cox reg

235 The multivariate-adjusted hazard ratios (HR) comparing beneficiaries with statin i

236 Risk was reported in hazard ratios (HR) with 95% confidence interval (CI).

237 Hazard ratios (HRs) and 95% CIs estimated using multivar

238 Hazard ratios (HRs) and 95% CIs for colorectal cancer in

239 onal hazards regression was used to estimate hazard ratios (HRs) and 95% CIs for overall survival (OS

240 Multivariable hazard ratios (HRs) and 95% confidence intervals (95%CI)

241 We estimated hazard ratios (HRs) and 95% confidence intervals (CIs) f

242 Cox regression models were used to calculate hazard ratios (HRs) and 95% confidence intervals (CIs) f

243 Cox regression models were used to calculate hazard ratios (HRs) and C statistics to determine predic

244 e used Cox models to estimate cause-specific hazard ratios (HRs) for 12 CVDs, adjusted for cardiovasc

245 h model was applied to estimate the adjusted hazard ratios (HRs) for 3 health transitions (healthy to

246 Hazard ratios (HRs) for clinical outcomes were calculate

247 Hazard ratios (HRs) for developing OAG with 95% CIs.

248 Hazard ratios (HRs) for incident parkinsonism per SD dec

249 s was inversely associated with incident HF: hazard ratios (HRs) of 0.99 per year (95% confidence int

250 e and time-varying confounders, we estimated hazard ratios (HRs) of death and of AIDS-defining illnes

251 Hazard ratios (HRs) were calculated from time of exposur

252 Hazard ratios (HRs) with 95% confidence intervals (CIs)

253 rd analysis was used to extract the adjusted hazard ratios (HRs) with adjustments for baseline age, s

254 s (RRs) for number of deaths/recurrences and hazard ratios (HRs), with 95% confidence intervals (CI),

255 her graft failure risks than males (adjusted hazard ratios 0-14 years: 1.51 [95% confidence intervals

256 os were not associated with 30-day mortality hazard ratios after controlling for baseline characteris

257 s between motor function and biomarkers, and hazard ratios analyzed.

258 rd models to calculate multivariate-adjusted hazard ratios and 95% confidence intervals (CIs) for FI

259 incident cardiac events were estimated with hazard ratios and 95% confidence intervals computed in C

260 on to examining melanoma incidence, melanoma hazard ratios and 95% confidence intervals for lithium e

261 Associations were estimated by hazard ratios and 95% confidence intervals using Cox mod

262 Men had lower survival; hazard ratios and 95% confidence intervals were 1.63 (1.

263 Hazard ratios and 95% confidence intervals were estimate

264 of cigarette smoking, was used to calculate hazard ratios and 95% confidence intervals.

265 With it, the hazard ratios at older ages are considerably higher, but

266 ars of age in ARIC and REGARDS, age-adjusted hazard ratios comparing blacks versus whites were 2.61 (

267 We calculated hazard ratios for 1-year adverse outcomes, including mor

268 The hazard ratios for incident coronary heart disease, strok

269 uations), we compared multivariable-adjusted hazard ratios for the composite outcome of incident ASCV

270 Health, Masters et al. reported age-specific hazard ratios for the contrasts in mortality rates betwe

271 ngle food frequency questionnaire, displayed hazard ratios of 1.31 (95% CI: 1.14, 1.51) and 1.07 (95%

272 The difference in hazard ratios of suicide-related events between lithium

273 Hazard ratios were calculated per 1% increase in LGE.

274 Hazard ratios were estimated with weighted Cox regressio

275 Hazard ratios were similar for patients below or above t

276 with ultralow-risk patients by Cox analysis (hazard ratios, 4.73 [95% CI, 1.38-16.22] and 4.54 [95% C

277 between readmissions and hospital survival (hazard ratios: first readmission 0.88, second readmissio

278 confidence interval, 0.61-0.78) and sisters hazard ratios=0.65 (95% confidence interval, 0.52-0.80),

279 bling): >/=10 cm difference between brothers hazard ratios=0.69 (95% confidence interval, 0.61-0.78)

280 Cox proportional hazards regression analyses were conducted between imagi

281 ted Kaplan-Meier curves and Cox proportional hazards regression analyses were used to compare OS of p

282 Univariate Cox proportional-hazards regression analysis showed that the CTC count in

283 In IPTW-adjusted Cox proportional hazards regression analysis, AC was associated with a si

284 :2 and among this cohort, a Cox proportional hazards regression model was used to identify predictors

285 Multivariable Cox proportional hazards regression models on the risk of a disease miles

286 We used Cox proportional hazards regression models to assess the association betw

287 stimated from multivariable Cox proportional hazards regression models.

288 Cox proportional hazards regression was performed in propensity score-mat

289 Multivariable Cox proportional hazards regression was used to adjust for potential conf

290 Cox proportional hazards regression was used to estimate hazard ratios (H

291 Cox proportional hazards regression was used to estimate HRs and 95% CIs

292 sing Kaplan-Meier analysis, Cox proportional hazards regression with the Harrell C-index, and net rec

293 led the hazard of CRC using Cox proportional hazards regression, accounting for within-cluster correl

294 Using multivariate Cox proportional hazards regression, the hazard ratio of HD in the first

295 r method, and multivariable Cox proportional hazards regression.

296 External political pressures deprived hazard-resistance entitlements of herders, which may exp

297 n be used by researchers and regulators in a hazard screening capacity to assess the potential of a p

298 equate laboratory protocols for analysis and hazard testing.

299 Combining this information with hazard (the magnitude of projected climate change within

300 Influenza is a serious hazard to human health that causes hundreds of thousands