ライフサイエンスコーパス: hazard

1 however, they also create catastrophic flood hazards.

2 urity in the face of drought and other water hazards.

3 mapping land susceptibility to wind erosion hazards.

4 hat are exposed to both wind and storm surge hazards.

5 ssion fatigue is a work-related professional hazard acquired when providing healthcare for patients.

6 Univariate and multivariate Cox proportional hazards analyses with time to progression to HGD and EAC

7 Unadjusted Cox proportional hazards analysis showed that eyes experiencing HP had a

8 Cox proportional hazards analysis, after adjusting for patient and hospit

9 ls available for the identification, and the hazard and risk assessment of these thyroid hormone disr

10 multaneously alleviate CO(2) -caused climate hazards and ever-increasing energy demands, as it can ut

11 o lose both from present exposure to natural hazards, and future climate-driven shifts in their distr

12 ice sheets represents a major socioeconomic hazard arising from anthropogenic warming, but the respo

13 eltas are increasingly vulnerable to coastal hazards as declining sediment supply and climate change

14 rries many of the same cardiovascular health hazards as smoking tobacco.

15 ch programs for drug development or chemical hazard assessment are designed to screen thousands of mo

16 This hazard can lead to physical and mental health problems f

17 Compared with isolated hazards, the multiple hazards/drivers associated with CEs can lead to higher e

18 ir exposure remained associated with a lower hazard for HHV-6B plasma detection (hazard ratio, 0.40;

19 isk scores had 1.23- and 1.65-fold increased hazard for major coronary events, respectively.

20 ad fewer ICU admissions (p=0.03) and reduced hazard for mortality (aHR 0.53, p=0.004; complete case a

21 to death of the user and simultaneously pose hazards for first responders.

22 Projections of future hazard from meteorological floods need to account for th

23 -fold (95% CI, 5.6-269.1; P<0.001) increased hazard in genotype-positive family members.

24 ntration in rice may even be a better health hazard indicator than the inorganic arsenic concentratio

25 blind people walking outside about potential hazard induced by nearby fast-moving objects are demonst

26 Classifications among these hazards, induced through quantifiable properties such as

27 This can be helpful to retrieve ENM-related hazard information and thus fill knowledge gaps in a com

28 antified the influence of a residential lead hazard intervention and dust control on children's urina

29 Features of this lead hazard intervention and measures to control dust may red

30 Natural hazards - mainly debris and mud flows, landslides, avala

31 Finally, a Cox proportional-hazard model revealed a hazard ratio of 9.5 (P < 0.005)

32 Cox proportional hazard model showed that risk factors were female sex (H

33 In a multivariate Cox proportional hazard model, HLA class II antibodies before transplanta

34 Cox proportional-hazards model (PHM) and propensity score matching were u

35 A Cox proportional hazards model adjusted for known clinical predictors sho

36 A multivariable Cox proportional hazards model was created to control for confounders ide

37 A Cox proportional hazards model was used to estimate the association of AA

38 nverse probability weighted Cox proportional hazards model, using a propensity score based on age, st

39 We used Cox proportional hazards modeling to estimate the hazard ratio (HR) and 9

40 Cox proportional hazards modeling was used to compare outcomes including

41 mic position (wealth) using Cox proportional hazards modelling.

42 Cox proportional hazard models estimated hazard ratios (HRs) for chronic

43 d ratios (HRs) derived from Cox proportional hazard models for time-to-first event endpoints and Coch

44 ing the count, we estimated Cox proportional hazard models to examine associations with incident HF h

45 ime to ART initiation using Cox proportional hazard models, and, in a post-hoc analysis, we used logi

46 ed using covariate-adjusted Cox proportional hazard models.

47 Cox proportional hazards models coupled with the least absolute shrinkage

48 Cox proportional hazards models estimated the association between baselin

49 ed using log-rank tests and Cox proportional hazards models to adjust for known adverse prognostic fa

50 Cox proportional hazards models were fit to identify whether size measure

51 Cox proportional hazards models were used to estimate hazard ratio (HR) a

52 Cox proportional hazards models were used to estimate the hazard ratio (H

53 Mixed-effects Cox proportional hazards models were used to examine associations between

54 ble logistic regression and Cox proportional hazards models were utilized.

55 We used Cox proportional hazards models, adjusted for high-dimensional propensity

56 lan-Meier and multivariable Cox Proportional Hazards models.

57 ssessed using multiadjusted Cox proportional hazards models.

58 mated HRs and 95% CIs using Cox proportional hazards models.

59 ry, were summarized by marginal proportional hazards models.

60 .2-fold (95% CI, 1.3-8.0; P=0.013) increased hazard of a composite of cardiac syncope, aborted cardia

61 sociated with a significantly lower rate and hazard of MACE at 5 years compared with no PCI (31.5% vs

62 exposure metrics that are based on specific hazards of the storm can help in designing tropical cycl

63 CI: 17, 33), and 32% (95% CI: 24, 39) lower hazards of type 2 diabetes compared with abstaining, res

64 t-use phases in which surface reactivity and hazard potential can be greatly altered by chemical expo

65 ients; P = .0034) and durability (P = .0081, hazard radio favoring CDAR, 0.094) of MRD-free CR.

66 r multiple surgeon characteristics (adjusted hazard rate 2.98, 95% CI 1.85-4.81).

67 rds regression model found that the adjusted hazard rate for loss-of-license actions for surgeons who

68 pared with the historical cohort (P < .0005; hazard rate, 0.43; 95% CI, 0.28 to 0.66).

69 notype, the effect of OSA showed an adjusted hazard ratio (95% confidence interval) of 1.54 (1.06-2.2

70 tion were associated with increased adjusted hazard ratio (aHR) for MACCE or all-cause mortality (aHR

71 86.4%, p < 0.001) than those with NOM, with hazard ratio (HR) 0.72 (95%CI 0.57-0.91).

72 AR was associated with a lower rate of MACE [hazard ratio (HR) 0.87 (0.80-0.94)], and a lower rate of

73 t associated with tumor recurrence [adjusted hazard ratio (HR) 1.02, 95% confidence interval (CI) 0.8

74 lated death was associated with: being male (hazard ratio (HR) 1.59 (95% confidence interval 1.53-1.6

75 s, women attending less than once per month (hazard ratio (HR) = 0.97, 95% confidence interval (CI):

76 roportional hazards modeling to estimate the hazard ratio (HR) and 95% confidence interval (CI) for t

77 rtional hazards models were used to estimate hazard ratio (HR) and 95% confidence interval (CI).

78 Primary outcomes included hazard ratio (HR) and cumulative incidence for SCZ and B

79 The hazard ratio (HR) for the imputed aggregate treatment ef

80 nal hazards models were used to estimate the hazard ratio (HR) of risk factors associated with rehosp

81 also improved in plasma recipients (adjusted hazard ratio (HR), 0.34; 95% CI, 0.13-0.89; chi-square t

82 lower rates of long-term mortality (adjusted hazard ratio (HR), 0.473; 95% CI, 0.392-0.571; p < 0.001

83 longed with capecitabine versus observation [hazard ratio (HR), 0.82; 95% CI, 0.63 to 1.06; P = .136]

84 lung primary was associated with longer DFS [hazard ratio (HR): 0.49, P = 0.008).

85 e viral load >=100'000 cps/mL (multivariable Hazard Ratio (mHR): 2.2, 95% CI: 1.3-3.6) and an AIDS de

86 tion (0.54 versus 1.25 events/patient-years, hazard ratio 0.43 [95% CI, 0.39-0.47], P<0.0001).

87 y associated with improved overall survival (hazard ratio 0.53, P < 0.001).

88 associated with improved survival [adjusted hazard ratio 0.61; (95% confidence interval (CI): 0.50-0

89 nd 40.8 months (36-48) in the placebo group (hazard ratio 0.69, 95% CI 0.58-0.82); 8-year landmark ov

90 11-10.78) with bortezomib and dexamethasone (hazard ratio 0.70 [95% CI 0.53-0.93], p=0.0075).

91 2.6 months (10.6-14.4) in the control group (hazard ratio 0.71 [95% CI 0.57-0.88], p=0.0016).

92 tion (1.67 versus 2.28 events/patient-years, hazard ratio 0.73 [95% CI, 0.68-0.78], P<0.0001).

93 11.1) for those assigned placebo (stratified hazard ratio 0.82, 95% CI 0.55-1.23; p=0.33).

94 10.4-15.0) in the chemotherapy group (n=207; hazard ratio 0.89, 95% CI 0.71-1.11; p=0.30).

95 ge the cumulative incidence (subdistribution hazard ratio 0.91, 95% confidence interval [CI] 0.49-1.6

96 significantly increased mortality (adjusted hazard ratio 0.99, 95% confidence interval 0.62-1.58) or

97 gher risk of AF as a single factor (adjusted hazard ratio 1.11, 95% confidence interval 1.08-1.13).

98 9-1.67, p=0.76) and the rate (cause-specific hazard ratio 1.36, 95%CI 0.71-2.63, p=0.36) of the prima

99 e was associated with increased risk of AAA [hazard ratio 1.37 (1.14, 1.66)], but the association was

100 ose who had early-life material deprivation (hazard ratio 1.38, 95% CI 1.27-1.51), persistent depriva

101 oth uni- and multivariate analysis (adjusted hazard ratio 3.05 and 1.88, respectively).

102 Ptrend = 0.001; and for EA, quintile5 vs. 1 hazard ratio = 0.79, 95% confidence interval: 0.64, 0.98

103 ed HNC and EA risk (for HNC, quintile5 vs. 1 hazard ratio = 0.81, 95% confidence interval: 0.71, 0.92

104 atal Tdap vaccination and ADHD in offspring (hazard ratio = 1.00, 95% confidence interval: 0.88, 1.14

105 ays; P < 0.001) and increased risk of death (hazard ratio = 4.1; P < 0.001).

106 ificantly associated with clinical outcomes (hazard ratio [95% confidence interval], 4.8 [2.6-9.0], P

107 had a similar 1-year risk of death (adjusted hazard ratio [adjHR]: 0.92; 95% CI: 0.46 to 1.84) and hi

108 hin the first month posttransplant (adjusted hazard ratio [aHR]: 2.493.494.89, P < 0.001), but a 62%

109 A in terms of biopsy-proven acute rejection (hazard ratio [confidence interval], 0.32 [0.11-0.90], P

110 0-82.7), respectively (low-risk vs high-risk hazard ratio [HR] 0.04, 95% CI 0.0-0.1, p<0.0001).

111 6.3 months (6.2-7.0) in group C (stratified hazard ratio [HR] 0.82, 95% CI 0.70-0.96; one-sided p=0.

112 SAF was an independent risk factor for CVEs (hazard ratio [HR] 1.12 per SD, 95% CI 1.03-1.22, p = 0.0

113 igher risk of death in univariable analysis (hazard ratio [HR] 2.13 [95% CI 1.49 to 3.02], P < 0.001)

114 4-0.34) with high-performing colonoscopists (hazard ratio [HR] 2.35; 95% CI 1.31-4.21; P = .004).

115 Male sex (hazard ratio [HR] 2.54, P = 0.02), diabetes (HR 2.39, P

116 associated with twice the 5-year mortality (hazard ratio [HR] = 2.11; 95% confidence interval [CI]:

117 catheter-related VTE than subjects with TLs (hazard ratio [HR] = 8.5; 95% confidence interval [CI], 3

118 oximately 8.5 years to 6 months in the past (hazard ratio [HR] for <50 vs >=500 cells/uL, 13.4; 95% c

119 adjusted overall mortality decreased by 24% (hazard ratio [HR] per year 0.976; 95% confidence interva

120 se mortality (13 studies, n = 36 986; pooled hazard ratio [HR], 0.40 [95% CI, 0.28-0.56) and hepatoce

121 entile) was associated with better survival (hazard ratio [HR], 0.45; P = 0.024), whereas a (68)Ga-DO

122 7.76 at an SSF of 2 showed better 5-year OS (hazard ratio [HR], 0.53 [95% confidence interval {CI}: 0

123 t (PFS population: 24.7 months v 9.4 months; hazard ratio [HR], 0.56 [95% CI, 0.37 to 0.84]).

124 s 18.2% of icosapent ethyl-treated patients (hazard ratio [HR], 0.69 [95% CI, 0.59-0.80]; P=0.000001)

125 previous use of any hormonal contraceptives (hazard ratio [HR], 0.70; 95% CI, 0.68-0.72), combined (H

126 empagliflozin versus placebo, respectively; hazard ratio [HR], 0.76; 95% CI, 0.67-0.87; P<0.0001).

127 On multivariable analysis, lung EHD (hazard ratio [HR], 0.7; 95% CI, 0.3-1.4), peritoneal EHD

128 nificantly reduced cardiovascular mortality (hazard ratio [HR], 0.82 [95% CI, 0.72-0.92]) and all-cau

129 for age, sex, and medical history (adjusted hazard ratio [HR], 0.83 [95% CI, 0.67-1.03]).

130 not significantly reduce first HHF/CV death (hazard ratio [HR], 0.88 [95% CI, 0.75-1.03]).

131 rdial infarction, stroke, and CVD mortality; hazard ratio [HR], 0.92 [95% CI, 0.80-1.06]) but were as

132 tiation with bevacizumab versus ranibizumab (hazard ratio [HR], 0.96 [95% confidence interval {CI}, 0

133 dently associated with worse OS and DFS (OS: hazard ratio [HR], 0.98; confidence interval [CI], 0.97-

134 clinical risk factors or high genetic risk (hazard ratio [HR], 1.02; absolute risk reduction [ARR],

135 long-term (beyond 12 mo) CVE were age at LT (hazard ratio [HR], 1.04; 95% confidence interval [CI], 1

136 = 1386 events; median follow-up, 25.2 years; hazard ratio [HR], 1.06 [95% CI, 0.89-1.26]), HF (n = 13

137 icantly associated with all-cause mortality (hazard ratio [HR], 1.49 [CI, 1.15 to 1.94]) and cardiova

138 apnea associated with increased risk of CKD (hazard ratio [HR], 1.51; 95% confidence interval [95% CI

139 ated with increased risk of macular atrophy (hazard ratio [HR], 1.70; 95% confidence interval [CI], 1

140 arly stage PDAC (13.5 months vs 23.3 months; hazard ratio [HR], 1.87; 95% confidence interval [CI]: 1

141 cantly increased the rate of immunogenicity (hazard ratio [HR], 1.90; 95% confidence interval [CI], 1

142 rtial or complete response rates (64% v 39%; hazard ratio [HR], 2.47; 95% CI, 1.30 to 4.71) and impro

143 32 versus 0.75 events per 100 patient-years (hazard ratio [HR], 3.05 [95% CI, 1.65 to 5.62]; P < 0.00

144 60 years at relapse had shorter second PFS (hazard ratio [HR], 3.0; P = .0029) and were mostly treat

145 ificantly associated with increased relapse (hazard ratio [HR], 6.38; 95% CI, 3.37 to 12.10; P < .001

146 ctive factor for graft and patient survival (hazard ratio [HR]: 0.67; P = .005, and HR: 0.65; P = .00

147 with both incident MACE and CV readmission (hazard ratio [HR]: 0.76; 95% confidence interval [CI]: 0

148 verall survival benefit versus placebo drug (hazard ratio [HR]: 0.87; 95% confidence interval [CI]: 0

149 anic patients had a higher rate of referral (hazard ratio [HR]: 1.22; 95% confidence interval [CI]: 1

150 n 73 (6.3%) patients in the prasugrel group (hazard ratio [HR]: 1.41; 95% confidence interval [CI]: 1

151 th 5-year cardiovascular mortality (adjusted hazard ratio [HR]: 2.18 [95% CI: 1.13 to 4.23] and 2.87

152 5.0 events per 1,000 person-years; adjusted hazard ratio [HR]: 2.35; 95% confidence interval [CI]: 2

153 ubstantial for severe arrhythmia (univariate hazard ratio [HR]: 2.70; 95% confidence interval [CI]: 1

154 milar risk of graft failure (subdistribution hazard ratio [sHR] 0.74; 95% confidence interval [CI], 0

155 Serum cystatin C (CysC; subdistribution hazard ratio [SHR], 1.58; 1.07-2.33), episodes of previo

156 The hazard ratio for 28-day mortality of diabetic patients,

157 The median hazard ratio for an association between a mental disorde

158 and 26.6% in the placebo-combination group (hazard ratio for death, 0.66; 95% CI, 0.50 to 0.88; P =

159 r use (median, 1.35 d vs. 1.04 d for normal; hazard ratio for discontinuation vs. normal, 0.78 [0.73-

160 ffect for female and male patients (adjusted hazard ratio for females: 0.90 [95% confidence interval:

161 In contrast, the adjusted hazard ratio for major amputations was 1.00 (95% CI, 0.9

162 confidence interval: 0.54 to 1.51]; adjusted hazard ratio for males: 0.76 [95% confidence interval: 0

163 increased risk for all-cause death (adjusted hazard ratio for moderate and severe degrees of malnutri

164 in the RA arm versus 83.7% in the RITA arm (hazard ratio for mortality, 0.53 [95% CI, 0.30-0.95]).

165 notype, the effect of OSA showed an adjusted hazard ratio of 0.69 (0.46-1.04; P value = 0.08).Conclus

166 Culture positivity at day 3 conferred a hazard ratio of 2.8 for requiring TPK (P = .03) but was

167 , a Cox proportional-hazard model revealed a hazard ratio of 9.5 (P < 0.005) for the two predicted gr

168 The mortality hazard ratio was high at 6.01 (95% CI, 4.02-10.72) withi

169 The adjusted hazard ratio was highest in patients who underwent isola

170 The survival hazard ratio was presented by machine-learning algorithm

171 significant in favor of the screening group (hazard ratio, 0.17; 95% CI, .03-.86).

172 with lenalidomide compared with observation (hazard ratio, 0.28; 95% CI, 0.12 to 0.62; P = .002).

173 icant lower in the ICD group (5% versus 13%, hazard ratio, 0.37 [95% CI, 0.15-0.95]) after 3 years fo

174 5% CI, 0.18-0.81] P=0.012), and circulating (hazard ratio, 0.38 [95% CI, 0.18-0.80] P=0.011) Ang 1-7/

175 usting for covariates, elevated equilibrium (hazard ratio, 0.38 [95% CI, 0.18-0.81] P=0.012), and cir

176 95% CI, 0.44-0.83]) and high fit (tertile 3: hazard ratio, 0.38 [95% CI, 0.24-0.59]) groups, respecti

177 a lower hazard for HHV-6B plasma detection (hazard ratio, 0.40; 95% confidence interval, 0.20-0.80).

178 k among participants with large CHIP clones (hazard ratio, 0.46 [95% CI, 0.29-0.73], P<0.001) but not

179 1.6 months for classifier-negative patients (hazard ratio, 0.49; 95% confidence interval, 0.280-0.86;

180 -0.86]) and without CRT (42.5% versus 66.9%, hazard ratio, 0.52 [95% CI, 0.39-0.69]; adjusted P(inter

181 d inverse probability of treatment weighting hazard ratio, 0.525; 95% CI, 0.240-1.145).

182 d inverse probability of treatment weighting hazard ratio, 0.539; 95% CI, 0.224-1.297) and at 60 days

183 y longer OS was observed with HER2 blockade (hazard ratio, 0.58; 95% CI, 0.34 to 0.97).

184 patients with prior CRT (48.6% versus 67.2%, hazard ratio, 0.60 [95% CI, 0.42-0.86]) and without CRT

185 and 62% lower among moderate fit (tertile 2: hazard ratio, 0.61 [95% CI, 0.44-0.83]) and high fit (te

186 0.0001) and coronary artery bypass grafting (hazard ratio, 0.61 [95% CI, 0.45-0.81]; P=0.0005).

187 reduced percutaneous coronary intervention (hazard ratio, 0.68 [95% CI, 0.59-0.79]; P<0.0001) and co

188 ce, 2.5 vs. 3.6 events per 100 person-years; hazard ratio, 0.69; 95% confidence interval [CI], 0.57 t

189 years compared with no PCI (31.5% vs 39.1%; hazard ratio, 0.77 [95% CI, 0.63-0.94]).

190 Apo M remained associated with death (hazard ratio, 0.78 [95% CI, 0.69-0.88]; P<0.0001) and th

191 (95% CI, -2.3 to 0.1) death per 1000 women (hazard ratio, 0.78 [CI, 0.63 to 0.95]) (a negative risk

192 ricular assist device/heart transplantation (hazard ratio, 0.85 [95% CI, 0.76-0.94]; P=0.001) in mode

193 diovascular readmission (19.7% versus 22.9%; hazard ratio, 0.85 [95% CI, 0.80-0.89]), and composite o

194 e PSA was inversely related with recurrence (hazard ratio, 0.9 per nanograms per milliliter of PSA; 9

195 2.2 with sotagliflozin and 2.4 with placebo (hazard ratio, 0.90; 95% CI, 0.73 to 1.12; P = 0.35).

196 r all-cause readmission (40.4% versus 44.1%; hazard ratio, 0.91 [95% CI, 0.88-0.95]), cardiovascular

197 s noninferior to sorafenib (10.2 and 9.2 mo [hazard ratio, 0.91; 95% confidence interval, 0.78-1.05])

198 t [95% CI, -11.3 to 12.3 percentage points]; hazard ratio, 0.93 [CI, 0.67 to 1.30]; P = 0.67).

199 <0.001) but not in individuals without CHIP (hazard ratio, 0.95 [95% CI, 0.89-1.01], P=0.08; P(intera

200 ortality or readmission (56.0% versus 58.4%; hazard ratio, 0.96 [95% CI, 0.93-1.00]).

201 ratio, 0.96 [95% CI, 0.75 to 1.24]; adjusted hazard ratio, 0.97 [95% CI, 0.76 to 1.25]).

202 2745 patients (11.9%) in the placebo group (hazard ratio, 0.97; 95.6% confidence interval [CI], 0.85

203 no change within minority-serving hospitals (hazard ratio, 0.99; 95% CI, 0.97-1.01).

204 increments on CVD outcomes, including MI (MI hazard ratio, 1.07 per unit mm Hg increase in DBP; P<0.0

205 22; P = 0.67), and long-term graft survival (hazard ratio, 1.07; 95% CI, 0.86-1.33; P = 0.55).

206 ch was not significantly different (adjusted hazard ratio, 1.07; 95% confidence interval, 0.68-1.68;

207 admissions had shorter use (median, 0.84 d; hazard ratio, 1.22 [1.12-1.33]; P < 0.001).

208 day mortality (34.7% vs 29.3%, respectively; hazard ratio, 1.3; 95% CI, 0.8-2.2; P = .26).

209 ncidence of death or initiation of dialysis (hazard ratio, 1.48; 95% CI, 1.04 to 2.11; P = 0.03).

210 mpensations in patients with DACLD (adjusted hazard ratio, 1.4; 95% confidence interval: 0.9, 1.9; P

211 I versus the CABG group (44.5% versus 31.9%; hazard ratio, 1.60 [95% CI, 1.15-2.22]; P=0.005).

212 rom left ventricular ejection fraction, 50%; hazard ratio, 1.63 [95% CI, 1.30-2.04]; P<0.001) were in

213 a history of >=2 HFHs in the past 12 months (hazard ratio, 1.77 [95% credible interval, 1.18-2.66], p

214 nconclusive tests (stress: 3.7% versus 2.0%, hazard ratio, 1.81, P=0.034; CTA: 5.0% versus 2.2%, haza

215 ratio, 1.81, P=0.034; CTA: 5.0% versus 2.2%, hazard ratio, 1.85; P=0.044) and positive tests (stress:

216 Male sex (hazard ratio, 1.89 [95% CI, 1.04-3.44]; P=0.04) and left

217 dicted higher incidence of both neovascular (hazard ratio, 11.036; 95% confidence interval [CI], 1.80

218 KD, with the highest risk for heart failure (hazard ratio, 11.40; 95% confidence interval, 8.38 to 15

219 ence interval [CI], 1.807-67.393) and total (hazard ratio, 11.425, 95% CI, 1.940-67.300) events.

220 erapy was associated with tumor progression (hazard ratio, 18.7; P < .0001), formation of distant met

221 risk difference, 1.07%; 95% CI, 0.46%-1.69%; hazard ratio, 2.07; 95% CI, 1.48 to 2.88).

222 Kidney dysfunction (hazard ratio, 2.28 [95% credible interval, 1.59-3.28], p

223 and shorter disease-specific survival times (hazard ratio, 23.1; P < .0001).

224 dent predictor of appropriate ICD therapies (hazard ratio, 3.47 [95% CI, 1.19-10.11]), and its integr

225 nd positive tests (stress: 8.3% versus 2.0%, hazard ratio, 3.50; CTA: 9.2% versus 2.2%, hazard ratio,

226 uent with FFR-guided PCI (24.9% versus 8.2%; hazard ratio, 3.51 [95% CI, 1.93-6.40]; P<0.001).

227 , hazard ratio, 3.50; CTA: 9.2% versus 2.2%, hazard ratio, 3.66; P<0.001).

228 ce of stroke than the conservative strategy (hazard ratio, 3.76; 95% CI, 1.52 to 9.32; P = 0.004) and

229 of a first hepatic decompensation (adjusted hazard ratio, 3.7; 95% confidence interval: 1.1, 12.6; P

230 ion was change in SUV(hetero) (PET1 to PET3; hazard ratio, 3.88; 95% CI, 1.24 to 12.1).

231 .2; P < .001) and those with DACLD (adjusted hazard ratio, 3.8; 95% confidence interval: 1.7, 9.5; P

232 subjects, and was associated with mortality (hazard ratio, 3.9; 95% CI, 1.09 to 14.14).

233 P < .0001), formation of distant metastases (hazard ratio, 32.1; P < .0001), and shorter disease-spec

234 tality in both patients with CACLD (adjusted hazard ratio, 7.4; 95% confidence interval: 2.7, 20.2; P

235 riate analysis, alemtuzumab (subdistribution hazard ratio, 9.0; 95% CI, 1.50-54.0; P = .02) was indep

236 On multivariate regression (odds ratio or hazard ratio, 95% confidence interval), diabetes (1.9, 1

237 ve quantified treatment effects by using the hazard ratio, which is difficult to interpret for a posi

238 tive for 1-year CV death/rehospitalizations (hazard ratio: 0.39; 95% confidence interval: 0.19 to 0.8

239 with remaining on the waiting list (adjusted hazard ratio: 0.58; 95% confidence interval: 0.36-0.95;

240 eduction only if 1-year LDL-C was <70 mg/dl (hazard ratio: 0.61; 95% confidence interval: 0.40 to 0.9

241 all-cause-mortality (7.6% vs. 9.7%; adjusted hazard ratio: 0.61; 95% confidence interval: 0.53 to 0.7

242 ween reporting CVD events and drug efficacy (hazard ratio: 0.68 vs. 0.67; p = 0.22).

243 lower risk of MACE (9.5% vs. 11.2%; adjusted hazard ratio: 0.77; 95% confidence interval: 0.68 to 0.8

244 lower risk for death or HF hospitalization (hazard ratio: 0.86; 95% confidence interval: 0.81 to 0.9

245 or HFH between 30 days and 2 years (adjusted hazard ratio: 0.91 per -5 mm Hg PASP; 95% confidence int

246 ith greater risk of subsequent MI or stroke (hazard ratio: 1.34; 95% confidence interval: 1.28 to 1.4

247 ) allele of CFH rs1329428 (P = 2.0 x 10(-3); hazard ratio: 1.74:95%CI: 1.16-2.59) after adjusting for

248 ignificantly associated with death (adjusted hazard ratio: 1.75; 95% CI: 1.37 to 2.24; p < 0.001) whi

249 isk) allele of ARMS2 A69S (P = 2.0 x 10(-4); hazard ratio: 2.18:95%CI: 1.47-3.24) and C(risk) allele

250 amputation or peripheral revascularization (hazard ratio: 8.13; 95% confidence interval: 7.96 to 8.2

251 rgery group compared with the control group (hazard ratio=0.72 [95% CI, 0.57-0.92], P=0.008).

252 zophrenia after substance-induced psychosis (hazard ratio=1.87, 95% CI=1.07- 3.26).

253 fferences in time to progression (unadjusted hazards ratio, 0.96 [95% CI, 0.75 to 1.24]; adjusted haz

254 onal propensity scores, to generate adjusted hazard ratios (aHR).

255 ompeting risks analysis to estimate adjusted hazard ratios (aHRs).

256 h risk factor, estimated all-cause mortality hazard ratios (HR) and population attributable fractions

257 th patients aged 1.0-9.9 years, adjusted AAP hazard ratios (HRa) were associated with higher age with

258 Adjusted hazard ratios (HRs) and 95% CIs were estimated in each d

259 Hazard ratios (HRs) and receiver operating characteristi

260 We used hazard ratios (HRs) derived from Cox proportional hazard

261 Cox proportional hazard models estimated hazard ratios (HRs) for chronic health conditions and 95

262 atching time variable), was used to estimate hazard ratios (HRs) for lung cancer incidence by sex, to

263 Cox regression was used to estimate hazard ratios (HRs) for severe liver disease at 5, 10, a

264 Hazard ratios (HRs) for the effects of radiotherapy timi

265 Hazard ratios (HRs) of CVD < 1 year after initiation of

266 cremental tertiles of time-varying total SB (hazard ratios [95% CI], 1.00 [referent], 1.15 [1.01-1.31

267 g to account for confounding when estimating hazard ratios and counterfactual risk functions.

268 ces in survival were markedly attenuated and hazard ratios approached 1.0.

269 odels for respective comparators resulted in hazard ratios below the null, except for vancomycin vs.

270 We estimated hazard ratios for all-cause mortality and deaths from ca

271 ds regression modeling was used to determine hazard ratios for coronary heart disease, CVD, and all-c

272 In multivariable analysis, the hazard ratios for CRC incidence after high-quality versu

273 The adjusted hazard ratios for high (vs.

274 Hazard ratios for mortality were calculated by using Cox

275 Compared with 2000 to 2004, the adjusted hazard ratios in 2013 to 2016 were 0.73 (95% CI, 0.62-0.

276 to 2.08) genetically, and with corresponding hazard ratios of 1.06 (95% CI: 1.05 to 1.08) and 1.06 (9

277 Cox regression was used to estimate hazard ratios of dementia by LC-SES scores in race-speci

278 horts, and estimated the incidence rates and hazard ratios of developing aortic aneurysm or dissectio

279 Hazard ratios per 5 BMI units, calculated using proporti

280 nt data within the UK Biobank: the estimated hazard ratios per standard deviation were 1.10 (95% conf

281 ciated with a decreased rate of progression (hazard ratios, 0.45 and 0.64, respectively).

282 sessed using time-dependent Cox proportional hazard regression analysis and landmark analysis.

283 A Cox proportional-hazards regression model found that the adjusted hazard

284 Cox proportional hazards regression modeling was used to determine hazard

285 esident-level analysis with Cox proportional hazards regression models adjusted for clustering by fac

286 Cox proportional hazards regression models were used to obtain age- and s

287 Multivariable logistic and Cox proportional hazards regression were applied.

288 ith those who did not using Cox proportional hazards regression with inverse probability weighting.

289 r 5 BMI units, calculated using proportional hazards regression, declined steadily with age at BMI as

290 We compared, by Cox proportional hazards regression, progression-free survival (PFS) afte

291 rvival was modeled by using Cox proportional hazards regression.

292 Compared with isolated hazards, the multiple hazards/drivers associated with CE

293 The analysis allowed the baseline hazard to vary according to neighborhood and was adjuste

294 atural nonchemical stressor posing potential hazards to organisms such as planktonic crustaceans.

295 To assess the expected inundation hazard, tsunami modeling was conducted based on several

296 alues of AUC (area under curve) for all five hazards using the best models are greater than 0.8, demo

297 ned constant (for example, 30% (8-47%) lower hazard when 20% versus 10% of a fixed 15 kJ kg(-1) d(-1)

298 er MVPA fraction was associated with a lower hazard when PAEE remained constant (for example, 30% (8-

299 determine increased awareness of peripheral hazards while wearing the DSpecs.

300 ium contamination is a growing environmental hazard worldwide.