stress ulcer prophylaxis versus placebo anders perner or...
TRANSCRIPT
Mette KragAnders PernerJørn WetterslevMatt P. WiseMorten Hylander Møller
Stress ulcer prophylaxis versus placeboor no prophylaxis in critically ill patientsA systematic review of randomised clinical trials withmeta-analysis and trial sequential analysis
Received: 30 July 2013Accepted: 25 September 2013Published online: 19 October 2013� Springer-Verlag Berlin Heidelberg andESICM 2013
Systematic review registrationThe International Prospective Register ofSystematic Reviews (PROSPERO), No.CRD42013004142.
Electronic supplementary materialThe online version of this article(doi:10.1007/s00134-013-3125-3) containssupplementary material, which is availableto authorized users.
M. Krag � A. Perner �M. Hylander Møller ())Department of Intensive Care, CopenhagenUniversity Hospital Rigshospitalet,Blegdamsvej 9, 2100 Copenhagen,Denmarke-mail: [email protected].: ?45-22555343URL: www.sup-icu.com
J. WetterslevCopenhagen Trial Unit, Centre for ClinicalIntervention Research, CopenhagenUniversity Hospital Rigshospitalet,Copenhagen, Denmark
M. P. WiseDepartment of Adult Critical Care,University Hospital of Wales, Cardiff, UK
Abstract Purpose: To assess theeffects of stress ulcer prophylaxis(SUP) versus placebo or no prophy-laxis on all-cause mortality,gastrointestinal (GI) bleeding andhospital-acquired pneumonia in adultcritically ill patients in the intensivecare unit (ICU). Methods: We per-formed a systematic review usingmeta-analysis and trial sequentialanalysis (TSA). Eligible trials wererandomised clinical trials comparingproton pump inhibitors or histamine 2receptor antagonists with either pla-cebo or no prophylaxis. Tworeviewers independently assessedstudies for inclusion and extracteddata. The Cochrane Collaborationmethodology was used. Risk ratios/relative risks (RR) with 95 % confi-dence intervals (CI) were estimated.The predefined outcome measureswere all-cause mortality, GI bleeding,and hospital-acquired pneumonia.Results: Twenty trials (n = 1,971)were included; all were judged ashaving a high risk of bias. There was
no statistically significant differencein mortality (fixed effect: RR 1.00,95 % CI 0.84–1.20; P = 0.87;I2 = 0 %) or hospital-acquired pneu-monia (random effects: RR 1.23,95 % CI 0.86–1.78; P = 0.28;I2 = 19 %) between SUP patients andthe no prophylaxis/placebo patients.These findings were confirmed in theTSA. With respect to GI bleeding, astatistically significant difference wasfound in the conventional meta-ana-lysis (random effects: RR 0.44, 95 %CI 0.28–0.68; P = 0.01; I2 = 48 %);however, TSA (TSA adjusted 95 %CI 0.18–1.11) and subgroup analysescould not confirm this finding. Con-clusions: This systematic reviewusing meta-analysis and TSA dem-onstrated that both the quality and thequantity of evidence supporting theuse of SUP in adult ICU patients islow. Consequently, large randomisedclinical trials are warranted.
Keywords Stress ulceration �Gastrointestinal bleeding �All-cause mortality � Meta-analysis �Trial sequential analysis �Stress ulcer prophylaxis
Introduction
Critically ill patients are at risk of stress-related gastro-intestinal (GI) bleeding [1]. The reported incidence of GI
bleeding in the intensive care unit (ICU) ranges from 2 to15 %, however this data derives from research published15–20 years ago [2, 3]. Intensive care practice haschanged substantially over recent decades and,
Intensive Care Med (2014) 40:11–22DOI 10.1007/s00134-013-3125-3 SYSTEMATIC REVIEW
consequently, the incidence of GI bleeding in critically illpatients may also have changed.
GI bleeding due to stress ulceration has been associ-ated with increased mortality and a prolonged length ofICU stay of 4–8 days [3, 4]. The results of older clinicaltrials indicate that stress ulcer prophylaxis (SUP) reducesthe frequency of GI bleeding in ICU patients, and SUP istherefore regarded as a standard of care in ICU as outlinedby the Surviving Sepsis Campaign guidelines [5]. How-ever, the rationale and level of evidence of SUP in ICUpatients has been questioned because of limited data,methodological flaws in some trials, possible increasedincidence of hospital-acquired pneumonia and Clostrid-ium difficile enteritis following the use of SUP andgeneral improvements in intensive care [1, 6–9]. Fur-thermore, there is a lack of studies comparing the use ofSUP versus no prophylaxis or placebo. Uncertainty overwhether routine SUP is indicated in critically ill patientstherefore exists amongst clinicians. As a result, there is aneed to weigh the risks of SUP in ICU patients against thebenefits of this approach in this patient group using up-to-date rigorous evidence-based methodology. The objectiveof our systematic review was to assess the effects of SUPversus placebo or no prophylaxis on all-cause mortality,GI bleeding and hospital-acquired pneumonia in criticallyill patients using strict bias evaluation, cumulative meta-analysis and trial sequential analysis (TSA).
Methods
This systematic review is based on the methodologyrecommended by the Cochrane Collaboration [10], andthe review has been prepared according to the PRISMAstatement [11]. The protocol is published in the Interna-tional Prospective Register of Systematic Reviews(PROSPERO), no. CRD42013004142.
Eligibility criteria
Potentially eligible trials had to be randomised, includeadult patients admitted to the ICU, have an interventiongroup that received SUP with proton pump inhibitors(PPIs) or histamine 2 receptor antagonists (H2RAs) andinclude a control group that received placebo or noprophylaxis. We included trials irrespective of languageand publication status. Trials were permitted to havemore than one intervention group. Exclusion criteriawere studies in animals, trials in patients aged\18 years, trials in patients not admitted to the ICUand trials only reporting non-patient-centred outcomemeasures [12], such as gastric pH and gastriccolonisation.
Search strategy
We framed the following focused research question: ‘‘IsSUP with PPIs or H2RAs in critically ill patients in theICU superior to placebo or no prophylaxis?’’
A population, intervention, comparator and outcomes-based question and literature search was created [13][Electronic Supplementary Material (ESM) 1].
The following databases were searched for literature:MEDLINE, including MeSH (January 1966 to March2013), EMBASE (January 1980 to March 2013) and theCochrane Library (Issue 2, March 2013). We also handsearched the reference lists of included trials and othersystematic reviews of SUP in the critically ill patients.The electronic literature search was last updated March20, 2013.
Study selection
Two authors (MK and MHM) independently reviewed alltitles and abstracts identified in the literature search andexcluded trials that were obviously not relevant. Theremaining trials were evaluated in full text. Disagree-ments were resolved by JW.
Data extraction
Two authors (MK and MHM) independently extractedinformation from each included trial using a dataextraction form. The extracted information included trialcharacteristics (year of publication, duration, country),characteristics of the trial participants (inclusion criteria,type of nutrition used), exclusion criteria, type of inter-vention/control (name, dosing, duration, route ofadministration, comparator) and outcomes. Trials werecategorised as using enteral nutrition—if patients receivedany volume of enteral nutrition. The predefined primaryoutcome measure of this review was all-cause mortality,and the predefined secondary outcomes were GI bleedingand pneumonia. The outcome measures were the same asthose defined by the authors of the original trials.
Risk of bias assessment
To determine the validity of the included trials, twoauthors (MK and MHM) independently assessed the riskof bias as advised by the Cochrane Collaboration [10],including the domains of random sequence generation,allocation concealment, blinding, incomplete outcomedata, selective outcome reporting, baseline imbalance andbias due to vested financial interest. If one or moredomains were judged as being high or unclear, we clas-sified the trial as having a high risk of bias [10].
12
Statistical analyses
Review Manager 5.1.7 was used for statistical analyses, andfor the TSA we used the TSA program version 0.9 beta(www.ctu.dk/tsa). For each included trial we calculated therelative risks (RR) with 95 % confidence intervals (CI) forthe three dichotomous outcome measures, and we pooledthese measures in the meta-analysis. Heterogeneity amongtrials was quantified with inconsistency factor (I2) [14] andthe Diversity (D2) statistics [15]. If the I2 statistic was 0, wereported the results from a fixed-effect model, and if the I2
statistic was [0, we reported results from both a fixed-effectand random-effects model. The cumulative meta-analysiswas challenged with the application of TSA—a sensitivityanalysis that widens the confidence intervals in case the dataare too sparse to draw firm conclusions [15–17] (ESM 2). Inaddition, the sensitivity analysis included application ofcontinuity correction in trials of zero events [18]. Risk ofsmall trial bias was assessed by Funnel plot asymmetry [19].
Subgroup analyses
We performed five predefined subgroup analyses and onepost hoc subgroup analysis: (1) high versus low risk ofbias trials (a possible increased intervention effect in trialswith a high risk of bias); (2) adequate versus inadequaterandom sequence generation, allocation concealment andblinding (a possible increased intervention effect in trialswith an inadequate random sequence generation, alloca-tion concealment and blinding); (3) use of PPIs versusH2RAs (a possible increased intervention effect in the PPIgroup); (4) medical versus surgical versus mixed ICU (apossible increased intervention effect in surgical patients);(5) use of enteral nutrition versus no enteral nutrition (apossible increased risk of hospital-acquired pneumonia inpatients receiving enteral nutrition); (6) placebo trialsversus no prophylaxis trials (a possible increased inter-vention effect in the no prophylaxis trials).
Results
Figure 1 summarises the results of the search: 20 trialswere included, all of which were published in English(Table 1) [20–39]. The main reasons for exclusion oftrials were (1) no relevant patient-centred outcome mea-sures were reported [40, 41] and (2) the trials wereconducted in a non-ICU setting (ESM 3) [42, 43].
Characteristics of trials
Of the 20 trials included in this review, 16 (80 %) weresingle-centre trials [20–29, 31, 34–38]. The four
multicentre trials were all from the USA and comprised atotal of 585 patients (30 % of the included patients) [30,32, 33, 39]. Twelve trials (60 %) used placebo as com-parator [20–22, 24, 31, 36, 37, 39], whereas the remainingtrials used no prophylaxis. In seven trials, patients werefed enterally [20, 22, 27, 32, 34, 36, 38].
Participants
The 20 included trials enrolled 1,971 adult patients in theICU. Seven trials included patients from mixed ICUs [21,
Fig. 1 Study flow diagram
13
Tab
le1
Char
acte
rist
ics
of
the
incl
uded
tria
ls
Fir
stau
thor
of
publi
shed
tria
l
No.
of
pat
ients
intr
ial
(n)
Set
ting/
countr
yT
rial
dura
tion
(month
s)
Inte
nsi
ve
care
unit
Ente
ral
nutr
itio
nIn
clusi
on
crit
eria
(popula
tion)
Excl
usi
on
crit
eria
Inte
rven
tion
Com
par
ator
Outc
om
es
Contr
ol
gro
up:
no
pro
phyla
xis
Apte
[20]
34
Sin
gle
centr
e/In
dia
Unknow
nM
edic
alY
esT
rach
eoto
mis
edpat
ients
wit
hte
tatu
sP
neu
monia
;S
UP
Ran
itid
ine
50
mg/e
ver
y6
hIV
No
pro
phyla
xis
Mort
alit
yN
oso
com
ial
pneu
monia
Over
tG
Ible
edin
gb
Bas
so[2
1]
116
Sin
gle
centr
e/It
aly
14
Surg
ical
No
Hig
hri
skpla
stic
-an
dneu
rosu
rger
ya
GI
ble
edin
g;
GI
surg
ery;
age
\12
yea
rs;
coag
ulo
pat
hy.
Cim
etid
ine
200
mg/e
ver
y6
hIV
or
ora
lly
inat
leas
t10
day
s
No
pro
phyla
xis
Over
tG
Ible
edin
g
Ben
-Men
achem
[22
]200
Sin
gle
centr
e/U
SA
10
Med
ical
Yes
Any
GI
ble
edin
g;
GI
surg
ery;
age
\18
yea
rs;
expec
ted
ICU
stay
\24
h;
SU
P;
anti
coag
ula
nts
;re
cent
surg
ery/
anae
sthes
ia;
hea
din
jury
;ra
ised
ICP
;gra
de
4hep
atic
ence
phal
opat
hy;
pre
gnan
cyor
lact
atat
ion
Cim
etid
ine
load
ing
dose
of
300
mg
IVan
din
fusi
on
titr
ated
tom
ainta
ingas
tric
pH
[4
No
pro
phyla
xis
Hosp
ital
mort
alit
yN
oso
com
ial
pneu
monia
Cli
nic
ally
signifi
cant
GI
ble
edin
gc
Dar
long
[24
]31
Sin
gle
centr
e/In
dia
Unknow
nM
ixed
No
MV
([24
hex
pec
ted
dura
tion)
and
NG
tube
insi
tu
GI
ble
edin
g;
SU
P;
coag
ulo
pat
hy;
anti
coag
ula
nts
Ran
itid
ine
50
mg/
ever
y8
hIV
No
pro
phyla
xis
Over
tG
Ible
edin
g
Mac
Dougal
l[3
1]
62
Sin
gle
centr
e/U
K18
Med
ical
No
Fulm
inan
thep
atic
fail
ure
GI
ble
edin
gM
etia
mid
e150
mg/
h(n
=10)
or
cim
etid
ine
100
mg/h
(n=
16)
IVy
giv
ing
pH
[5
No
pro
phyla
xis
Mort
alit
yO
ver
tG
Ible
edin
g
Reu
sser
[36
]40
Sin
gle
centr
e/S
wit
zerl
and
26
Surg
ical
No
Acu
tetr
aum
atic
or
sponta
neo
us
bra
inin
jury
and
neu
rosu
rger
yan
dM
V[
48
h
GI
ble
edin
g;
age
\15
yea
rs;
GI
surg
ery;
PU
D;
SU
P
Ran
itid
ine
50
mg/
ever
y8/6
hIV
titr
ated
tom
ainta
ingas
tric
pH
[4
No
pro
phyla
xis
Mort
alit
yO
ver
tG
Ible
edin
g
Ruiz
-San
tana
[37
]49
Sin
gle
centr
e/S
pai
n14
Mix
edY
esM
V(e
xpec
ted
dura
tion
[6
day
s)an
dm
etab
oli
cst
ress
;no
shock
and
no
renal
or
hep
atic
dis
ease
;to
tal
par
ente
ral
nutr
itio
n
GI
ble
edin
g;
GI
surg
ery;
PU
D;
SC
I;A
KI;
hep
atic
fail
ure
,ca
taboli
cin
dex
score
B0;
SU
P
Ran
itid
ine
50
mg/
ever
y8
hIV
No
pro
phyla
xis
Mort
alit
yO
ver
tG
Ible
edin
g
Zin
ner
[39
]200
Mult
icen
tre/
US
A24
Surg
ical
No
Expec
ted
ICU
dura
tion
[48
hG
Ible
edin
g;
GI
surg
ery;
PU
DC
imet
idin
e300
mg/e
ver
y6
hIV
duri
ng
ICU
stay
No
pro
phyla
xis
Mort
alit
yO
ver
tG
Ible
edin
g
14
Ta
ble
1co
nti
nu
ed
Fir
stau
thor
of
publi
shed
tria
l
No.
of
pat
ients
intr
ial
(n)
Set
ting/
countr
yT
rial
dura
tion
(month
s)
Inte
nsi
ve
care
unit
Ente
ral
nutr
itio
nIn
clusi
on
crit
eria
(popula
tion)
Excl
usi
on
crit
eria
Inte
rven
tion
Com
par
ator
Outc
om
es
Contr
ol
gro
up:
pla
cebo
Burg
ess
[23
]34
Sin
gle
centr
e/U
SA
9S
urg
ical
No
Sev
ere
hea
din
jury
and
GC
SB
10
PU
D;
GI
inju
ry;
SU
P;
ora
lin
take
Ran
itid
ine
6.2
5m
g/h
IVfo
rup
to72
h
Pla
cebo
Mort
alit
yO
ver
tG
Ible
edin
g
Fri
edm
an[2
5]
25
Sin
gle
centr
e/U
SA
18
Med
ical
No
MV
GI
ble
edin
g;
AK
I;S
UP
;pre
gnan
cyC
imet
idin
e300
mg/e
ver
y6
hIV
Pla
cebo
Over
tG
Ible
edin
g
Gro
ll[2
6]
221
Sin
gle
centr
e/C
anad
a21
Mix
edN
oA
ny
GI
ble
edin
g;
AK
I;S
UP
;pre
gnan
cy;
dru
gover
dosa
ge;
AM
I
Cim
etid
ine
300
mg/e
ver
y6
hIV
Pla
cebo
Mort
alit
yO
ver
tG
Ible
edin
g
Hal
lora
n[2
7]
50
Sin
gle
centr
e/U
SA
21
Surg
ical
Yes
Sev
ere
hea
din
jury
Bra
indea
th;
PU
D;
pre
gnan
cy;
GI
inju
ry;
sever
ehep
atic
or
renal
dis
ease
Cim
etid
ine
300
mg/e
ver
y4
hIV
for
up
to3
wee
ks
Pla
cebo
Over
tG
Ible
edin
g
Han
isch
[28
]114
Sin
gle
centr
e/G
erm
any
12
Surg
ical
No
MV
PU
D;
GI
ble
edin
g;
age\
18
yea
rs;
tran
spla
nte
dpat
ients
(kid
ney
,li
ver
,hea
rt);
pneu
monia
;G
Isu
rger
y
Ran
itid
ine
50
mg
93
IVP
lace
bo
Mort
alit
yN
oso
com
ial
pneu
monia
Cli
nic
ally
signifi
cant
GI
ble
edin
g
Kan
toro
va
[29
]208
Sin
gle
centr
e/C
zech
Rep
ubli
c
29
Surg
ical
Yes
MV
(expec
ted
dura
tion
[48
h)
or
coag
ulo
pat
hy;
age
[18
yea
rs;
NG
tube
insi
tu
GI
ble
edin
g;
GI
surg
ery;
pneu
monia
;S
UP
;P
UD
;an
tico
agula
nts
;A
KI,
coag
ulo
pat
hy;
life
expec
tancy
\3
month
s
Om
epra
zole
40
mg
IV;
Fam
oti
din
e40
mg
92
IV
Pla
cebo
Hosp
ital
mort
alit
yN
oso
com
ial
pneu
monia
Cli
nic
ally
signifi
cant
GI
ble
edin
g
Kar
lsta
dt
[30
]87
Mult
icen
tre/
US
AU
nknow
nM
ixed
No
At
leas
tone
of
the
foll
ow
ing:
maj
or
thora
cic
or
abdom
inal
surg
ery;
mult
iple
trau
ma;
hypote
nsi
on;
hypovole
mic
shock
;se
psi
s;ac
ute
resp
irat
ory
fail
ure
GI
ble
edin
g;
hep
atic
fail
ure
;A
KI;
SU
P;
pre
gnan
cyor
lact
atat
ion;
age
\16
yea
rs;
hyper
secr
etory
dis
ord
ers
Cim
etid
ine
300
mg
load
ing
dose
,fo
llow
edby
infu
sion
at50
mg/e
ver
yhour
Pla
cebo
Mort
alit
yN
oso
com
ial
pneu
monia
Cli
nic
ally
signifi
cant
GI
ble
edin
g
15
Ta
ble
1co
nti
nu
ed
Fir
stau
thor
of
publi
shed
tria
l
No.
of
pat
ients
intr
ial
(n)
Set
ting/
countr
yT
rial
dura
tion
(month
s)
Inte
nsi
ve
care
unit
Ente
ral
nutr
itio
nIn
clusi
on
crit
eria
(popula
tion)
Excl
usi
on
crit
eria
Inte
rven
tion
Com
par
ator
Outc
om
es
Mar
tin
[32
]131
Mult
icen
tre/
US
A7
Mix
edY
esE
xpec
ted
ICU
stay
[36
h;
NG
tube
insi
tu;
atle
ast
one
of
the
foll
ow
ing:
maj
or
surg
ery;
mult
iple
trau
ma;
hypote
nsi
on;
hypovole
mic
shock
;se
psi
s;ac
ute
resp
irat
ory
fail
ure
;ja
undic
e;burn
[30%
GI
ble
edin
g;
pre
gnan
cyor
lact
atat
ion;
age
\16
yea
rs;
GI
surg
ery;
SU
P;
anti
coag
ula
nts
Cim
etid
ine
300
mg
load
ing
dose
,fo
llow
edby
50
mg/h
IVfo
rup
to7
day
s
Pla
cebo
30-d
aym
ort
alit
yN
oso
com
ial
pneu
monia
Over
tG
Ible
edin
g
Met
z[3
3]
167
Mult
icen
tre/
US
A20
Surg
ical
No
Sev
ere
hea
din
jury
;G
CS
B10;
NG
tube
inpla
ce
GI
ble
edin
g;
age
\18
yea
rs;
expec
ted
ICU
stay
\72
h;
burn
s[20
%;
AK
I;P
UD
;co
agulo
pat
hy;
SU
P
Ran
itid
ine
6.2
5m
g/h
IVfo
rup
to5
day
s
Pla
cebo
Mort
alit
yN
oso
com
ial
pneu
monia
Over
tG
Ible
edin
g
Peu
ra[3
4]
39
Sin
gle
centr
e/U
SA
Unknow
nM
edic
alY
esE
xpec
ted
ICU
stay
[5
day
sG
Ible
edin
g;
age\
18
yea
rs;
GI
surg
ery;
AM
I;pre
gnan
cy
Cim
etid
ine
300
mg/e
ver
y6
hIV
for
3–14
day
s
Pla
cebo
Mort
alit
yO
ver
tG
Ible
edin
g
Pow
ell
[35]
41
Sin
gle
centr
e/U
KU
nknow
nS
urg
ical
No
Sch
edule
dco
ronar
yar
tery
bypas
sgra
ftpat
ients
inIC
U
PU
D;
GI
surg
ery;
SU
P;
sever
eal
lerg
y;
AK
I;hep
atic
dis
ease
;an
tico
agula
nts
Ran
itid
ine
50
mg/
ever
y8
hIV
;om
epra
zole
80
mg
load
ing
dose
foll
ow
edby
40
mg/e
ver
y8
hby
bolu
sIV
;om
epra
zole
80
mg
load
ing
dose
foll
ow
edby
40
mg/e
ver
y8
hby
infu
sion
Pla
cebo
Mort
alit
yO
ver
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16
24, 26, 30, 32, 37, 38], eight trials included surgical ICUpatients only (including trauma and neurosurgery) [23, 27–29, 33, 35, 36, 39] and five trials included patients inmedical ICUs [20, 22, 25, 31, 34]. Inclusion and exclusioncriteria varied considerably between trials (Table 1).
Interventions
Twenty trials evaluated H2RAs and two trials evaluatedPPIs. Seven trials assessed ranitidine [20, 23, 24, 28, 33, 36,37], ten trials assessed cimetidine [21, 22, 25–27, 30, 32, 34,38, 39], two trials assessed omeprazole [29, 35] and threetrials evaluated more than one intervention (e.g. both PPIand H2RA) [29, 31, 35]. The route of administration wasintravenously in 19 trials [20, 22–39] and either orally orintravenously in one trial [21]. SUP dosing and duration oftreatment varied across trials (Table 1).
Bias risk assessment
No trials were judged to be of low risk of bias in all sixdomains (Fig. 2). The main reasons for high risk of biaswere inadequate random sequence generation, allocationconcealment or blinding (ESM 4). One trial had adequaterandom sequence generation, allocation concealment andblinding [28] and was included in the subgroup analysisof adequate versus inadequate random sequence genera-tion, allocation concealment and blinding. Eight trials hadpotential financial bias because of sponsorship by phar-maceutical companies [20, 23, 25, 27, 30–33].
Outcome measures
All-cause mortality
Mortality data were obtained from 15 trials including1,604 patients [20, 22, 23, 26–32, 34–37, 39]. The meta-analysis of all 15 trials showed no significant difference inmortality in patients treated with SUP compared withthose treated with placebo or no prophylaxis (fixed effect:RR 1.00, 95 % CI 0.84–1.20; P = 0.87; I2 = 0 %;Fig. 3). Application of an empirical continuity correctionof 0.01 in the two no-event trials did not change the result.The subgroup analysis of trials using PPIs versus trialsusing H2RAs showed no increased intervention effect inthe PPI group (test of interaction P = 0.68). The sub-group analysis of trials with a low risk of bias versus ahigh risk of bias could not be done because there were notrials with a low risk of bias. In the subgroup analysis oftrials with adequate versus inadequate random sequencegeneration, allocation concealment and blinding and inthe placebo versus no prophylaxis subgroup analysis, noincreased intervention effect was found in the inadequate
Fig. 2 Risk of bias summary. Review of authors’ judgements abouteach risk of bias item for each included study. Red High risk, greenlow risk, yellow unclear
17
group or in the no prophylaxis group. The subgroupanalysis according to type of ICU, showed no increasedintervention effect in the surgical ICU trials (test ofinteraction P = 0.11). Finally, no subgroup differencewas found between enterally fed patients and non-enter-ally fed patients (test of interaction P = 0.11). TheFunnel plot raised concern about small trial bias (ESM 8).
TSA showed that 57 % (1,594 patients) of the requiredinformation size to detect or reject a 20 % relative riskreduction (RRR) corresponding to 2,794 patients wasaccrued. The cumulative Z curve did not even touch theconventional boundary for harm or benefit (P [ 0.05) orthe trial sequential monitoring boundary for harm orbenefit (ESM 5). However, the Z curve did reach thefutility area, hereby excluding a 20 % RRR in mortalityby using PPIs or H2RA.
GI bleeding
All 20 trials (n = 1,971) had data on GI bleeding [20–39].The conventional meta-analysis showed a statisticallysignificant difference in GI bleeding in patients treatedwith SUP compared with those treated with placebo or noprophylaxis (fixed effect: RR 0.41, 95 % CI 0.31–0.53;
P = 0.01; I2 = 48 %; random effects: RR 0.44, 95 % CI0.28–0.68) (Fig. 4). Application of an empirical conti-nuity correction of 0.01 in the four no-event trials did notchange the result. In the subgroup analysis of trials usingPPIs versus trials using H2RAs, no increased interventioneffect in the PPI group was found (test of interactionP = 0.54). No trials had a low risk of bias, so the sub-group analysis of low versus high risk of bias trials couldnot be done. The adequate versus inadequate randomsequence generation, allocation concealment and blindingsubgroup analysis, and the placebo versus no prophylaxissubgroup analysis showed no signs of an increasedintervention effect in the inadequate group or in the noprophylaxis group. The subgroup analysis according totype of ICU showed no increased intervention effect inthe surgical ICU trials (test of interaction P = 0.92). Nostatistically significant subgroup difference betweenenterally fed patients and parenteral nutrition was found(test of interaction P = 0.15). The risk of smaller trialbias was low according to the Funnel plot (ESM 8).
TSA showed that only 22 % (1,881 patients) of therequired information size of 8,707 patients was accrued.The cumulative Z curve crossed the conventionalboundary for benefit (P \ 0.05), but not the trialsequential monitoring boundary for benefit (ESM 9).
Fig. 3 Stress ulcer prophylaxis (SUP) and all-cause mortality. Size of squares for risk ratio (RR) reflects the weight of the trial in thepooled analyses. Horizontal bars 95 % Confidence intervals (CI)
18
Hospital-acquired pneumonia
Seven trials comprising 1,008 patients reported data onhospital-acquired pneumonia. The meta-analysis showedno statistically significant difference in pneumonia inpatients treated with SUP compared with those treatedwith placebo or no prophylaxis (fixed effect: RR 1.16,95 % CI 0.84–1.58; P = 0.28; I2 = 19 %; randomeffects: RR 1.23, 95 % CI 0.86–1.78) (ESM 6). Appli-cation of an empirical continuity correction of 0.01 inthe two no-event trials did not change the result. Thesubgroup analysis of trials using PPIs versus trials usingH2RAs showed no increased intervention effect in thePPI group (test of interaction P = 0.56). The subgroupanalysis of trials with a low risk of bias versus a highrisk of bias could not be done. In the subgroup analysisof adequate versus inadequate random sequence gener-ation, allocation concealment and blinding, no signs ofan increased intervention effect in the inadequate groupwas found. An increased intervention effect in the pla-cebo group was found in the placebo versus noprophylaxis subgroup analysis (test of interaction
P = 0.02); however, significant statistical heterogeneitywas present (I2 = 80 %). The subgroup analysisaccording to type of ICU showed no increased inter-vention effect in the surgical ICU trials (test ofinteraction P = 0.11). Finally, no statistically significantincreased risk of hospital-acquired pneumonia in theenteral nutrition group was found (test of interactionP = 0.06). No evidence of smaller trial bias was presentin the Funnel plot (ESM 8).
TSA showed that a mere 12 % (1,008 patients) of therequired information size of 8,694 patients was accrued.The cumulative Z curve did not touch the conventionalboundary for harm or benefit, or the trial sequentialmonitoring boundary for harm or benefit (ESM 7).
Discussion
In the present systematic review using meta-analysis andTSA on SUP in adult critically ill patients in the ICU,SUP was not statistically significantly different from
Fig. 4 SUP and gastrointestinal (GI) bleeding. Size of squares for RR reflects the weight of the trial in pooled analyses. Horizontal bars95 % CI
19
placebo or no prophylaxis in terms of mortality, GIbleeding and pneumonia.
Mortality
The pooled analysis of mortality showed neither benefitnor harm of SUP with PPIs or H2RAs. No subgroupdifferences were present. The sensitivity analysis withTSA confirmed the finding in the conventional meta-analysis. Importantly, the TSA showed that it is unlikelythat SUP will result in a relative mortality reduction of20 % if further trials are conducted in adult ICU patients.
According to the risk of bias assessment [10], all trialshad a high risk of bias. Thus, the pooled analyses may beinfluenced by the poor quality of existing trials, which couldresult in inflated point estimates and thus make interpretationdifficult. Furthermore, the Funnel plot asymmetry with theabsence of small negative trials increases the risk of over-estimating the effect of SUP [44, 45].
GI bleeding
The conventional pooled analysis of GI bleeding showeda benefit of H2RAs. However, this finding could not beconfirmed in the analysis of trials with adequate randomsequence generation, allocation concealment and blinding(n = 1), and in the TSA. Consequently, an inflated pointestimate in the conventional pooled analysis can be sus-pected. No subgroup differences were present.Considering the high risk of bias and sparse data, a gen-uine benefit of SUP on the risk of GI bleeding in adultICU patients may be questioned.
Hospital-acquired pneumonia
No statistically significant benefit or harm of SUP on the riskof hospital-acquired pneumonia was demonstrated in theconventional meta-analysis or TSA. This was confirmed inthe subgroup analyses. The overall high risk of bias in thetrials warrants careful interpretation of the results because ofan increased risk of falsely inflated estimates [44, 45].
Strengths and limitations of the review
The compliance with the recommendations of the Coch-rane Collaboration is a strength of the present systematicreview. The recommendations implemented in our reviewinclude a published protocol, an up-to-date literaturesearch with no language restrictions, an independent lit-erature search, data extraction and bias risk assessment bytwo authors and the inclusion of trials irrespective ofpublication and language status. In addition, we reduced
the risk of random error in the meta-analysis with theapplication of TSA to increase the robustness of theanalyses; this methodology has not been used in existingmeta-analyses on SUP in the ICU. We excluded trialsmerely reporting non-patient-centered outcomes in orderto make the results relevant for clinical practice. Thesubgroup analysis of trials with adequate versus inade-quate random sequence generation, allocationconcealment and blinding might have resulted in spuriousfindings. However, this analysis was introduced with theaim of estimating a possible bias effect. The heterogeneityof the included trials was considerable. We did not definethe three outcome measures evaluated; rather, we used thedefinitions proposed by the authors, which may haveresulted in trial heterogeneity. Most of the included trialshave been conducted in high-risk patients, which must bekept in mind when interpreting the results. Overall, sta-tistical heterogeneity did not seem to be a big issue, andwe have reported both fixed-effect and random-effectspooled estimates when heterogeneity was present.
Relation to other reviews and implication for futureresearch
No previous systematic reviews have been published onPPIs versus placebo or no prophylaxis, and only a fewsystematic reviews have evaluated H2RAs versus placeboor no prophylaxis. In 2010, Marik and colleagues sug-gested that in patients who are fed enterally, SUP does notreduce the risk of GI bleeding from stress ulcers and mayeven increase the risk of pneumonia and death [1].However, there are a number of limitations to the reviewof these authors as three published trials were not iden-tified or included [24, 25, 31], the risk of bias andprecision assessment was not conducted as recommendedby GRADE [46], no study protocol was published orregistered and the increased risk of random errors in theconventional meta-analysis was not evaluated. Theseissues may have contributed to the discrepancies in rela-tion to the present review. In 1996, Cook and colleaguesconducted a thorough and comprehensive systematicreview of SUP in critically ill patients [47]. However, theuse of PPIs in the treatment of peptic ulcer disease beganafter 1996; consequently, the effect of PPIs was notevaluated in this meta-analysis. A number of methodo-logical discrepancies between the Cook review and ourreview do exist. Not surprisingly, the placebo/no pro-phylaxis part of the Cook review included fewer trials andpatients. Secondly, a different risk of bias assessment wasused. Thirdly, no published protocol was identified.Finally, the increased risk of random errors due to pos-sible multiple updating and sparse data was not assessed.Despite these dissimilarities, the pooled estimates in theconventional meta-analysis were of the same magnitudeas those observed in our study.
20
The authors of recently published systematic reviewshave suggested that PPIs significantly lower the risk of GIbleeding, without influencing the risk of hospital-acquiredpneumonia, mortality or length of stay, as compared toH2RAs [6, 48]. However, whether PPIs are superior toH2RAs may not be relevant when H2RAs have notunequivocally been shown to be superior to placebo. Thissituation has the imminent risk that even though PPIs maybe superior to H2RAs, they may not be better than pla-cebo or no prophylaxis.
The TSA included in the present review adds impor-tant information to the area of SUP in adult ICU patients,as they highlight the lack of firm evidence for the use ofSUP in this population. To ensure patient safety, well-powered trials with a low risk of bias are urgently needed.
Conclusion
This systematic review using meta-analysis and TSA hasdemonstrated that the quality and quantity of evidence forthe use of SUP in adult ICU patients is low and that thereis no firm evidence for benefit or harm of SUP as com-pared to placebo or no prophylaxis. Consequently, agenuine benefit of SUP in adult ICU patients may bequestioned, and large randomised clinical trials should beconducted to answer the question of whether critically illpatients in the ICU should be treated with SUP or not.
Conflicts of interest None.
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