ライフサイエンスコーパス: hospital mortality

1 cess to TAVR, TAVR utilization rates, and in-hospital mortality.

2 R, 4.86 [1.92-12.28]) had higher rates of in-hospital mortality.

3 for mechanical ventilator support and higher hospital mortality.

4 ly associated with risk of intubation and in-hospital mortality.

5 mination to identify patients at risk for in-hospital mortality.

6 women, lower severity of illness, and lower hospital mortality.

7 monary organ dysfunction, and substantial in-hospital mortality.

8 included ICU/hospital length of stay and ICU/hospital mortality.

9 ncidences of PPCI, delayed treatment, and in-hospital mortality.

10 There were no significant changes in ICU and hospital mortality.

11 nd approach of thoracic aortic repair and in-hospital mortality.

12 s per nurse ratio was not associated with in-hospital mortality.

13 tay without increases in ICU readmissions or hospital mortality.

14 64-53.61, p = 0.001) were associated with in-hospital mortality.

15 Our primary outcome measure was in-hospital mortality.

16 was independently associated with increased hospital mortality.

17 sion Assessment Method for the ICU-7, and in-hospital mortality.

18 s (Clavien-Dindo >=III), readmission, and in-hospital mortality.

19 There was no difference in in-hospital mortality.

20 diation analysis and the primary outcome was hospital mortality.

21 n excellent negative predictive value for in-hospital mortality.

22 ar ejection fraction and known predictors of hospital mortality.

23 nificantly associated with differences in in-hospital mortality.

24 orrelates with the risk of intubation and in-hospital mortality.

25 pital lengths of stay, complications, and in-hospital mortality.

26 ntifies patients with CS at high risk for in-hospital mortality.

27 rease) were independently associated with in-hospital mortality.

28 m duration, higher delirium severity, and in-hospital mortality.

29 therapies was independently associated with hospital mortality.

30 e independently associated with increased in-hospital mortality.

31 cy department to ICU time is associated with hospital mortality.

32 s not associated with significantly improved hospital mortality.

33 with STEMI and shock and its influence on in-hospital mortality.

34 and hospital factors were associated with in-hospital mortality.

35 ically incomplete resection, or 3) 30-day/in-hospital mortality.

36 letal muscle mass has been shown to increase hospital mortality.

37 riod for ED-LOS, HLOS, complications, and in-hospital mortality.

38 artile 4 were also associated with higher in-hospital mortality.

39 ge (PDD, or "against medical advice") and in-hospital mortality.

40 ical cure, acute kidney injury (AKI), and in-hospital mortality.

41 There was no significant difference in hospital mortality.

42 ta to derive 126 decision rules that predict hospital mortality.

43 he day of admission with risk-adjusted acute hospital mortality.

44 ls suffered significantly higher rates of in-hospital mortality.

45 ntly associated with an increased risk of in-hospital mortality.

46 ventilation or patients who evolved with in-hospital mortality.

47 ical ventilation strategies might improve in-hospital mortality.

48 er nurse ratio was associated with higher in-hospital mortality.

49 delirium duration, delirium severity, and in-hospital mortality.

50 gth of stay, hospital length of stay, and in-hospital mortality.

51 pt of invasive mechanical ventilation and in-hospital mortality.

52 or-1 were not found to be associated with in-hospital mortality.

53 ED dwell times, complications, HLOS, and in-hospital mortality.

54 cant difference between groups, including in-hospital mortality (1.7% for uncemented fixation vs 2.0%

55 sociated with a significant difference in in-hospital mortality (1.9% overlapping vs 1.6% nonoverlapp

56 for a marginally significant decrease in in-hospital mortality (-1.1%; 95% CI, -2.2% to -0.1%).

57 ry, IT was not associated with additional in-hospital mortality (11.0% for IT vs 12.1% for no IT, abs

58 ted during influenza season had increased in-hospital mortality (11.0% vs. 5.8%, p = 0.024) and incre

59 cranial hemorrhage (7.7% versus 4.8%) and in-hospital mortality (12.6% versus 8.9%), but these differ

60 Neither total in-hospital mortality (13/46 [28%] versus 22/104 [21%]; P =

61 9% versus 8.6%, P=0.12), no difference in in-hospital mortality (2.2% versus 2.2% P=0.99), and a grea

62 revascularization had significantly lower in-hospital mortality (2.8% versus 4.0%; P=0.002), myocardi

63 fter the onset of septic shock and 30-day in-hospital mortality; 2) determine whether the effect of v

64 pital length of stay (median 10 vs 11 d), in-hospital mortality (22.6% vs 29.4%), or 30-day mortality

65 emale sex was an independent predictor of in-hospital mortality (23.0% versus 21.7%; adjusted odds ra

66 eipt of early HAT was associated with higher hospital mortality (28.2% vs. 19.7%; P < 0.001; adjusted

67 Hospital mortality (29.75% vs 21.1%), combined mortality

68 Secondary outcomes included in-hospital mortality, 30-day mortality from admission, and

69 sicker and had more comorbidities and higher hospital mortality (32% vs. 45%; P < 0.05).

70 th of stay (median 19 vs 8 d), and higher in-hospital mortality (33% vs 17%) (p < 0.001 for all compa

71 was not associated with an effect on ICU or hospital mortality (33% vs 37%; odds ratio, 1.18 [0.92-1

72 7; 95% CI, 0.65-0.70) and higher rates of in-hospital mortality (4.9% versus 2.8%; odds ratio, 1.81;

73 ESRD patients had a higher in-hospital mortality (5.1% vs. 3.4%; p < 0.01), although t

74 , 1.90 [95% CI, 1.63-2.22]; P<0.0001) and in hospital mortality (5.6% versus 4.2%; relative risk, 1.3

75 s 22/104 [21%]; P = 0.3) nor attributable in-hospital mortality (9/46 [20%] versus 13/104 [12%]; P =

76 The estimated cumulative incidence of in-hospital mortality 90 days after the initiation of ECMO

77 me, the estimated cumulative incidence of in-hospital mortality 90 days after the initiation of ECMO

78 , PCI was associated with a lower risk of in-hospital mortality across quintiles of propensity score

79 iving noninvasive ventilation had similar in-hospital mortality across the ICU utilization spectrum b

80 1,959; 44.6%) were associated with lower in-hospital mortality (adjusted hazard ratio [aHR]: 0.53; 9

81 s, the Crs was independently associated with hospital mortality (adjusted odds ratio per ml/cm H(2)O

82 Higher LVSWI was associated with lower in-hospital mortality (adjusted odds ratio, 0.72 per 10 gxm

83 tion-associated major bleeding had higher in-hospital mortality (adjusted odds ratio, 1.49; 95% CI, 1

84 sor was associated with increased odds of in-hospital mortality (adjusted odds ratio, 1.88; 95% CI, 1

85 AI shock stage was associated with increased hospital mortality (adjusted odds ratio: 1.53 to 6.80; a

86 -comparisons <0.001) and increase in TAVR in-hospital mortality (adjusted OR, 6.13 [95% CI, 1.97-19.1

87 95% CI 0.3-6.9), increased probability of in-hospital mortality (adjusted subdistribution hazard rati

88 ivariable and multivariable predictors of in-hospital mortality, adjusted for confounding with an a p

89 characteristic curves for discriminating in-hospital mortality, adjusting for baseline characteristi

90 was a significant center effect on the mean hospital mortality, after adjustment on individual progn

91 evant hospitalization outcomes, including in-hospital mortality, after controlling for key demographi

92 were largely insensitive to variations in in-hospital mortality, age at baseline, or costs of rehospi

93 Twenty-eight studies observed greater in-hospital mortality among all levels of prolonged ICU sta

94 nced crystalloids versus saline on 30-day in-hospital mortality among critically ill adults with seps

95 amined the rates of revascularization and in-hospital mortality among Medicaid beneficiaries versus p

96 ween the proposed SCAI staging system and in-hospital mortality among patient with heart failure and

97 d for invasive mechanical ventilation and in-hospital mortality among patients admitted with asthma e

98 The rates of in-hospital mortality among pregnant women with acute strok

99 ary and noncardiopulmonary complications, in-hospital mortality and 30-day readmission for HFrEF comp

100 dpoints included length of hospital stay, in-hospital mortality and adverse events.

101 Secondary outcomes included hospital mortality and care processes.

102 serum lactate (> 3 mmol/L) at predicting in-hospital mortality and compared these results to those f

103 regression models for the outcomes of acute hospital mortality and death or prolonged ICU length of

104 was independently associated with higher in-hospital mortality and greater resource utilization.

105 The primary outcomes were in-hospital mortality and in-hospital major bleeding.

106 r association with patient outcomes, such as hospital mortality and length of stay, was analyzed.

107 Although in-hospital mortality and major adverse cardiovascular even

108 rates of all-cause mortality at 30 days, in-hospital mortality and mortality after discharge (p < 0.

109 We assessed in-hospital mortality and need for postdischarge care among

110 operator volume was associated with lower in-hospital mortality and no difference in postdischarge MA

111 emorrhage may have the greatest impact on in-hospital mortality and organ failure.

112 To describe trends in hospital mortality and rates of discharge home among the

113 ects of every additional organ failure on in-hospital mortality and resource utilization were assesse

114 d dual-energy CT variables correlate with in-hospital mortality and short-term outcomes for contusion

115 l-energy CT variables that correlate with in-hospital mortality and short-term outcomes for contusion

116 Secondary outcomes were in-hospital mortality and stroke.

117 The main outcomes of interest were in-hospital mortality and the occurrence of de-novo ventric

118 ures in RCTs such as lymph nodes harvest, in-hospital mortality, and locoregional cancer recurrence.

119 elirium rate, intensive care unit mortality, hospital mortality, and physical function- and mental he

120 gression was used to compare the odds for in-hospital mortality, and the average marginal effects wer

121 patients, was an independent predictor of in-hospital mortality, and was associated with increased ri

122 se, stimulant-only use had higher risk of in-hospital mortality (aRR 1.26, 95% CI 1.03-1.46).

123 f increasing severity of hyponatremia and in-hospital mortality assessed using multivariable logistic

124 s to describe contemporary management and in-hospital mortality associated with blunt thoracic aortic

125 In-hospital mortality associated with sepsis after trauma d

126 rence in 30-day postsurgical mortality or in-hospital mortality between the 2 groups.

127 ay (p < 0.05) and there was no difference in hospital mortality between undocumented immigrants and d

128 la use, and associated clinical outcomes (in-hospital mortality, bleeding requiring transfusion, acut

129 , 1.62; 95% CI, 1.27 to 2.04) higher odds of hospital mortality, but no appreciable difference in DNR

130 severity adjusted odds ratio (odds ratio) of hospital mortality, but this was slower among trauma pat

131 cterize COVID-19-associated morbidity and in-hospital mortality by race/ethnicity.

132 on presentation had a trend toward lower in-hospital mortality compared with those who presented wit

133 Overall in-hospital mortality decreased from 22.90% pre-Affordable

134 The risk-adjusted acute hospital mortality decreased significantly within each a

135 ICU and hospital mortality depended mainly on the severity of th

136 Secondary outcomes included in-hospital mortality, diarrhea, and biochemical features o

137 hanical ventilation, length of ICU stay, and hospital mortality, did not change.

138 een organ failure and calories exposure with hospital mortality during the first week of acute respir

139 tics) was used to determine risk-adjusted in-hospital mortality for all distal pancreatectomies (DP),

140 lve surgery on rates of valve surgery and in-hospital mortality for endocarditis is not known.

141 admissions, resource use, and risk-adjusted hospital mortality for older patients, admitted over a 2

142 In-hospital mortality for patients admitted to the hospital

143 coronavirus 2 positive patients and a lower hospital mortality for patients treated in the ICU for c

144 was an independent, negative predictor of in-hospital mortality for patients who experienced an SVC l

145 regardless of IDU status, and a reduction in-hospital mortality for patients with IE.

146 ge, 3-5 d] vs 4 d [3-6 d]; p = 0.349), or in-hospital mortality (four vs three deaths; relative risk

147 ich may be associated with a high rate of in-hospital mortality from these conditions compared with t

148 were independently associated with higher in-hospital mortality, greater resource utilization, and fe

149 was independently associated with higher in-hospital mortality (hazard ratio 1.89, 95% CI 1.20-2.97)

150 (hazard ratio, 1.99; 95% CI, 1.51-2.63) and hospital mortality (hazard ratio, 1.93; 95% CI, 1.48-2.5

151 ease, 1.14% [95% CI, 0.75%-1.53%]), lower in-hospital mortality/hospice discharge (absolute decrease,

152 matic intracranial hemorrhage (sICH), and in-hospital mortality/hospice discharge.

153 d diabetes, no significant differences in in-hospital mortality, ICU admission, or mechanical ventila

154 relationships between these variables and in-hospital mortality in a log-binomial model.

155 In-hospital mortality in cancer-related sepsis was 27.9% ve

156 f IFN-alpha2b was associated with reduced in-hospital mortality in comparison with no admission of IF

157 perglycemia ratio, independently predicts in-hospital mortality in critically ill patients across the

158 Hospital mortality in each SCAI shock stage was stratifi

159 retable, and highly accurate predictor of in-hospital mortality in elderly ES patients up to age 85 y

160 Several factors predict in-hospital mortality in fibrotic interstitial lung disease

161 tively, the patients per nurse ratio with in-hospital mortality in ICUs.

162 age is a well-recognized risk factor for in-hospital mortality in patients receiving extracorporeal

163 tive performance of prognostic scores for in-hospital mortality in patients with aSAH.

164 ention-to-treat primary analyses examined in-hospital mortality in the four pairwise comparisons of e

165 und between patients per nurse ratios and in-hospital mortality in The Netherlands.

166 30.0%, 15.7%, 7.3%, and 1.0% and unadjusted hospital mortality in these stages was 3.0%, 7.1%, 12.4%

167 hanical ventilation-related predictors of in-hospital mortality included achieving early targeted pla

168 Unadjusted clinical predictors of in-hospital mortality included age (unit odds ratio, 1.05;

169 Hospital mortality increased from 31% in acute respirato

170 d longer in hospital post-ICU discharge, and hospital mortality increased with age, but the majority

171 Hospital mortality is lower for trauma than other nonele

172 Co-primary endpoints were in-hospital mortality, length of stay (LOS), and cost.

173 endpoints were antimicrobial consumption, in-hospital mortality, length of stay (LOS), and the incide

174 ondary outcomes included an evaluation of in-hospital mortality, length of stay, infusion-related rea

175 Hospital mortality, long-term survival, recommencement o

176 r case-fatality rates (mostly reported as in-hospital mortality) (moderate- to high-strength evidence

177 Outcomes were in-hospital mortality, mortality rates based on insurance t

178 In-hospital mortality (MViV=6.3%, MViR=9%, ViMAC=18%; P=0.0

179 was AKI, and secondary outcomes included in-hospital mortality, need for ventilatory support, intens

180 he mean LVSWI was 38+/-14 gxmin/m(2), and in-hospital mortality occurred in 6% of patients.

181 In-hospital mortality occurred in 95 patients (3.6%), organ

182 ar risk of in-hospital adverse events and in-hospital mortality (odds ratio, 0.36; 95% CI, 0.12-1.07;

183 odds ratio, 0.36; 95% CI, 0.32-0.40) and in-hospital mortality (odds ratio, 0.48; 95% CI 0.40-0.58).

184 ssociated with decreased risk-adjusted acute hospital mortality (odds ratio, 0.94; 95% CI, 0.90-0.99;

185 en between higher strain and increased acute hospital mortality (odds ratio, 1.04; 95% CI, 1.00-1.10;

186 tin levels were associated with increased in-hospital mortality (odds ratio, 1.518 per log ug/L [95%

187 io on day 1 were associated with a higher in-hospital mortality (odds ratios, 1.19 and 1.17, respecti

188 S implied a negative predictive value for in-hospital mortality of 98.1% (93.1-99.5%).

189 The hospital mortality of patients admitted to the ICU was 1

190 olume and examined in relation to average in-hospital mortality of the highest volume quintile.

191 ity, 30-day mortality from admission, and in-hospital mortality or 30-day mortality post-discharge.

192 Primary outcomes were in-hospital mortality or complications (major: thromboembol

193 more likely to have a combined outcome of in-hospital mortality or discharge to hospice (25.9% versus

194 nificantly associated with differences in in-hospital mortality or postoperative complication rates b

195 Outcomes were assessed as in-hospital mortality or recovery.

196 -3.23) while older age was a predictor of in-hospital mortality (OR 4.18; 95% CI 1.94-9.04).

197 its administration in 24 hours decreased in-hospital mortality (OR = 0.25, 95% CI [0.09-0.67]; OR =

198 currence of paravalvular regurgitation or in-hospital mortality, or both.

199 monia) with each unfavorable outcome [ie, in-hospital mortality, organ failure, prolonged hospital st

200 For the primary outcome of acute hospital mortality, our parsimonious risk model consisti

201 dial injury was associated with increased in-hospital mortality particularly if echocardiographic abn

202 uniformly associated with increased risk of hospital mortality, particularly for cirrhosis (adjusted

203 iated with patient's predicted risk of acute hospital mortality, particularly when its standardized b

204 Adjusted hospital mortality (primary) and length of hospitalizati

205 oagulation use was associated with increased hospital mortality, prolonged length of stay, and higher

206 The outcomes evaluated were in-hospital mortality, Rancho Los Amigos scale (RLAS) score

207 In-hospital mortality ranged from 2.1% to 4.8% in the inter

208 Descriptive analyses showed that the in-hospital mortality rate for patients identified with end

209 ients with COVID-19 and is associated with a hospital mortality rate of >60%.

210 The in-hospital mortality rate was 10.0%, and at a median follo

211 f 2859 sepsis cases were included and the in-hospital mortality rate was 14.4%.

212 Overall, the in-hospital mortality rate was 38.8% among patients with a

213 The overall in-hospital mortality rate was 59.9%.

214 Hospital mortality rate was significantly higher within

215 observed beneficial effects of BCG on the in-hospital mortality rate were entirely nonspecific.

216 need for surgical intervention and a high in-hospital mortality rate.

217 vs. 2013: 56%, p < 0.001), with declining in-hospital mortality rates (1999: 64% vs. 2013: 46%; p < 0

218 sess for changes in valve replacement and in-hospital mortality rates after the public reporting init

219 his study was to examine whether elevated in-hospital mortality rates in lower volume hospitals are o

220 High quality of care, with in-hospital mortality rates less or equal to high-volume ho

221 vs histamine-2 receptor blockers resulted in hospital mortality rates of 18.3% vs 17.5%, respectively

222 y with hospital lengths of stay (LOS) and in-hospital mortality rates using linear and logistic regre

223 Overall ICU and hospital mortality rates were 26% and 37%, respectively.

224 Importantly, in-hospital mortality rates were almost 385-fold higher amo

225 ent specific risk factors or only predict in-hospital mortality rates.

226 scharge delay and patient outcomes including hospital mortality, readmission to ICU, and length of ho

227 In-hospital mortality remained high in AMI admissions treat

228 vities Score per nurse ratio on day 1 and in-hospital mortality remained significant (odds ratios, 1.

229 approach to identify patients at risk for in-hospital mortality remains under investigation.

230 the primary end point was a composite of in-hospital mortality, renal replacement therapy, or severe

231 31-1.47) and 4.32 (95% CI, 4.06-4.59) for in-hospital mortality, respectively.

232 g presence or absence of CA, provided robust hospital mortality risk stratification.

233 This reduction in hospital mortality risk was seen across the 4 different

234 atively and IT does not confer additional in-hospital mortality risk.

235 The primary outcome was in-hospital mortality; secondary outcomes were invasive mon

236 Women had a higher unadjusted rate of in-hospital mortality than did men in both patients with ST

237 LVSWI had better discrimination for hospital mortality than left ventricular ejection fracti

238 d less aggressively and experience higher in-hospital mortality than men.

239 Trauma patients had a lower hospital mortality than nonelective, nontrauma patients

240 Black race was not associated with higher in-hospital mortality than white race, after adjustment for

241 ise, there was a significant reduction of in-hospital mortality to 4.8% (n = 186) after 2013 (P = 0.0

242 Outcomes of interest included in-hospital mortality, use of cardiac interventions, hospit

243 End points of interest included in-hospital mortality, use of coronary angiography, percuta

244 ss-sectional observational study of COVID-19 hospital mortality using data from the SIVEP-Gripe (Sist

245 therapy (within 2 d of hospitalization) with hospital mortality using multivariable modeling and prop

246 stic curve of the LUCK classification for in-hospital mortality was 0.89 (P=0.001), and of the Killip

247 Overall in-hospital mortality was 10% (1/10), peaking 25% in patien

248 The hospital mortality was 14% and was independently associa

249 3% developed sepsis, 6% septic shock, and in-hospital mortality was 14%.

250 For the full cohort of patients, in-hospital mortality was 19.0%, and the median intensive c

251 Overall in-hospital mortality was 2.1%.

252 The overall median in-hospital mortality was 2.62% (interquartile range, 1.72-

253 Overall in-hospital mortality was 20.3% (95% CI, 18.2%-22.4%).

254 Unadjusted 30-day in-hospital mortality was 26.3% in New York State and 22.0%

255 In-hospital mortality was 30% for venovenous extracorporeal

256 In-hospital mortality was 31% for the total cohort, but hig

257 In-hospital mortality was 35.0% with a high viral load (Ct<

258 In-hospital mortality was 5% and 90-day mortality 8%.

259 In-hospital mortality was 50% among patients with AKI versu

260 atients, ICU length of stay was 9.5 days, in-hospital mortality was 56%, and 6-month mortality was 19

261 Overall in-hospital mortality was 56%, but rates were higher when i

262 In-hospital mortality was 8.8% for the entire patient cohor

263 Although in-hospital mortality was 9%, 35% of survivors demonstrated

264 All-cause 30-day in-hospital mortality was 958 (4.0%) in Improving Pediatric

265 ing Activities Score per nurse ratio with in-hospital mortality was analyzed using logistic regressio

266 Hospital mortality was analyzed using multivariable logi

267 The influence of PCI on in-hospital mortality was assessed by quintiles of propensi

268 Risk for in-hospital mortality was associated with increasing SCAI s

269 In regression analysis, in-hospital mortality was associated with longer CPB time.

270 In-hospital mortality was evaluated for association with SC

271 Their in-hospital mortality was higher (35% vs 19%, P = .001), de

272 Unadjusted in-hospital mortality was higher in patients who underwent

273 In the subgroup analysis, in-hospital mortality was lower in patients operated in cen

274 Compared with the Northeast, in-hospital mortality was lower in the Midwest (adjusted od

275 en clinical risk factors, biomarkers, and in-hospital mortality was modelled using Cox proportional h

276 In-hospital mortality was not associated with the use of ph

277 Adjusted in-hospital mortality was not different across quartiles of

278 entiles: 3.1 to 9.6 days]; p = 0.003) and in-hospital mortality was not significantly different (6.2%

279 oreal membrane oxygenation initiation and in-hospital mortality was observed.

280 Hospital mortality was over 14% and increased with subse

281 ion of variables independently predicting in-hospital mortality was performed by multivariable logist

282 between periods of high ICU strain and acute hospital mortality was strongest when bed census was com

283 %) and 7 (4%) respectively, while overall in hospital-mortality was 16 (8%).

284 The primary outcome, in-hospital mortality, was analyzed using a multivariable l

285 FA >= 2 and maximum qSOFA >= 2 to predict in-hospital mortality were 33% and 69%, respectively.

286 Adjusted odds of in-hospital mortality were 39% greater in patients who met

287 Rates of in-hospital mortality were 5.2%, 18.6%, and 31.7% in patien

288 Predictors for major complications and in-hospital mortality were assessed in multivariable logist

289 Age-standardized rates of operations and in-hospital mortality were calculated and mapped.

290 length of stay (HLOS); complications; and in-hospital mortality were compared before (PRE) and after

291 )/transient ischemic attack incidence and in-hospital mortality were extracted.

292 Odds of in-hospital mortality were higher among SARS-CoV-2 stroke p

293 ariables that were associated with higher in-hospital mortality were increasing age and presentation

294 No differences in hospital mortality were seen between warfarin- and direc

295 ve care unit, mechanical ventilation, and in-hospital mortality) were captured from electronic health

296 hemostatic intervention, transfusion, and in-hospital mortality, were compared with consensus categor

297 , and comorbidities contributed to higher in-hospital mortality, while distal perfusion cannula was p

298 cation improved Killip ability to predict in-hospital mortality with a net reclassification improveme

299 iated with increased odds ratio of 30-day in-hospital mortality, with the strength of association dep

300 lab, and output events for prediction of in-hospital mortality without variable selection.