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Review – Bladder Cancer
Immediate Post–Transurethral Resection of Bladder Tumor
Intravesical Chemotherapy Prevents Non–Muscle-invasive
Bladder Cancer Recurrences: An Updated Meta-analysis on
2548 Patients and Quality-of-Evidence Review
Nathan Perlis a,b,c,*, Alexandre R. Zlotta a,b,d, Joseph Beyene c,e, Antonio Finelli a,b,f,Neil E. Fleshner a,b,f, Girish S. Kulkarni a,b,g
a University Health Network, Toronto, Ontario, Canada; b University of Toronto, Department of Surgery, Division of Urology, Toronto, Ontario, Canada;c Institute of Health Policy, Management and Evaluation, University of Toronto, Toronto, Ontario, Canada; d Mount Sinai Hospital, Department of Surgery,
Division of Urology, Toronto, Ontario, Canada; e Department of Clinical Epidemiology and Biostatistics, McMaster University, Hamilton, Ontario, Canada;f Institute of Medical Science, University of Toronto, Ontario, Canada; g Institute for Clinical Evaluative Sciences, University of Toronto, Ontario, Canada
E U R O P E A N U R O L O G Y 6 4 ( 2 0 1 3 ) 4 2 1 – 4 3 0
ava i lable at www.sciencedirect .com
journal homepage: www.europeanurology.com
Article info
Article history:
Accepted June 7, 2013Published online ahead ofprint on June 18, 2013
Keywords:
Bladder cancer
Chemotherapy
Disease prevention
Single instillation
Systematic review
Abstract
Context: Non–muscle-invasive bladder cancer (NMIBC) commonly recurs, requiringinvasive and costly transurethral resection of bladder tumor (TURBT). A meta-analysisof seven trials published in 2004 demonstrated that intravesical chemotherapy (IVC)following TURBT reduces recurrences. Despite European Association of Urology en-dorsement, adoption of this practice has been modest.Objective: To investigate whether immediate postoperative IVC prolongs the recurrence-free interval (RFI) and early recurrences (ERs) in light of new trial data and to explore thequality of evidence supporting its use.Evidence acquisition: A systematic literature review of random controlled trials (RCTs)published before March 2013 was performed using the Medline, Embase, and Cochranedatabases. Trials examining NMIBC recurrence for adults receiving IVC immediatelyfollowing TURBT were included. RFI was estimated by hazard ratio (HR), and ER wasestimated by absolute risk reduction (ARR) of recurrences within 1 yr of TURBT. Bothoutcomes were synthesized using random-effects models. Risk of bias was assessedusing the Cochrane Collaboration risk-of-bias tool, and quality of evidence for eachoutcome was assessed using the Grading of Recommendations, Assessment, Develop-ment, and Evaluation system.Evidence synthesis: Thirteen studies with 2548 patients were included. IVC prolongedRFI by 38% (HR: 0.62; 95% confidence interval [CI], 0.50–0.77; p < 0.001; I2: 69%), and ERswere 12% less likely in the intervention population (ARR: 0.12; 95% CI, �0.18 to �0.06;p < 0.001, I2: 0%). The number needed to treat to prevent one ER was 9 (95% CI,6–17 patients). There was high risk of bias present in 12 of 13 publications. Qualityof evidence for RFI was very low and low for ERs.Conclusions: Our updated meta-analysis supports that IVC prolongs RFI and reduces ERsof NMIBC when administered immediately after TURBT. However, contemporary meth-odology suggests low evidence quality for examined outcomes. Thus RCTs with carefulrandomization and blinding are still warranted to clarify the usefulness of immediatepostoperative IVC in this population.
# 2013 European Association of Urology. Published by Elsevier B.V. All rights reserved.
* Corresponding author. Division of Urology, Department of Surgical Oncology, Princess MargaretHospital, University Health Network, 610 University Avenue, M5G 2M9, Toronto, Ontario, Canada.Tel. +1 416 946 4501, ext. 3698; Fax: +1 416 598 9997.E-mail addresses: [email protected], [email protected] (N. Perlis).
0302-2838/$ – see back matter # 2013 European Association of Urology. Published by Elsevier B.V. All rights reserved.http://dx.doi.org/10.1016/j.eururo.2013.06.009
1. Introduction
Bladder cancer (BCa) is the most expensive solid tumor to
treat mainly due to the high recurrence rate of its non–
muscle-invasive form (confined to the urothelium [Ta] or
lamina propria [T1]) [1]. Many non–muscle-invasive BCas
(NMIBCs) are amenable to treatment with transurethral
resection of bladder tumor (TURBT) alone. However,
despite the therapeutic impact of TURBT, BCa recurrence
rates can be as high as 80% [2]. Attempts have been made
to decrease these high recurrence rates and consequently
their associated costs.
It is hypothesized that one of the mechanisms for
early recurrence of NMIBC following TURBT is implanta-
tion of floating cancers cells into the bladder urothelium
following resection [3]. To address this so-called
seeding phenomenon, many investigators have utilized
an immediate postoperative instillation of intravesical
chemotherapy (IVC) to eradicate any free-floating cancer
cells after a complete TURBT [4]. Evidence supporting
such a practice was strengthened in 2004 by Sylvester
et al., who performed a meta-analysis incorporating all
immediate postoperative chemoprophylaxis trials pub-
lished to date [5]. They demonstrated a significant
improvement in the likelihood of recurrence for NMIBC
patients who received IVC after TURBT. The number
needed to treat (NNT) to prevent one NMIBC recurrence
was 8.5.
Despite the published evidence favoring postoperative
chemoprophylaxis, its adoption has been modest
because many urologists are reluctant to use it [6]. Cited
reasons for nonadherence include burden of extra
postoperative nursing care and coordination difficulties
between operating room, pharmacy, and recovery room
[6]. Critics of IVC believe that NMIBC recurrences can be
managed with simple office-based fulguration [7]. Some
trials suggest that the benefit of IVC may be limited
to a select subset of patients with small tumors [8]. A
more current review without meta-analysis from
2009 estimates that IVC chemotherapy may have a
NNT closer to 20 for NMIBC recurrence prevention [9].
Both the American Urological Association and the
European Association of Urology guidelines continue to
recommend immediate post-TURBT IVC for suspected
NMIBC [10,11].
Due to the ongoing conflict between the available
synthesized data and the practices of urologists and the
large number of studies performed since the first meta-
analysis in 2004, we believed an updated meta-analysis
with robust methodology was required. Our primary
objective was to synthesize current evidence-based
data regarding the use of immediate post-TURBT IVC in
NMIBC by (1) investigating the impact of postoperative IVC
on recurrence-free interval (RFI) and early recurrences
(ERs) in light of newly published clinical trial data, and
(2) exploring the quality of evidence available in the
included studies.
2. Evidence acquisition
2.1. Criteria for study inclusion/exclusion
2.1.1. Studies
Randomized controlled trials (RCTs) published in any
language were eligible for inclusion. Abstracts from RCTs
were eligible for inclusion only if adequate data (as defined
by inclusion criteria below) were available.
2.1.2. Participants
Patient-level inclusion criteria included age (adults �18 yr),
and histology showing pathologically confirmed urothelial or
transitional cell carcinoma. Other histologic subtypes of BCa
(eg, squamous, adenocarcinoma) were excluded because
they are rare, portend worse outcomes, and are not typically
managed with IVC [12]. Tumor characteristics included
pathologically confirmed low-grade (previously G1 or G2)
and low-stage BCa (Ta or T1). Patients with any component of
carcinoma in situ (CIS), muscle invasion, or metastatic
disease were not eligible.
2.1.3. Interventions
Intervention-level inclusion criteria were determined based
on the following categories:
� Chemotherapy: Trials using any IVC were included. Those
trials examining alternative routes of administration
(ie, intravenous, oral, intramuscular injection) were
excluded.
� Timing: IVC administration within 24 h following TURBT.
� Other interventions: Trial arms with any mandated
additional interventions aside from placebo IVC were
excluded.
2.1.4. Outcomes
Studies were only included if they contained at least one of
the following primary outcome measures: RFI following
randomization as measured by hazard ratio (HR) and/or ER
within 1 yr of randomization as measured by absolute risk
reduction (ARR; also termed risk difference). Recurrences
were identified by cystoscopy and biopsy.
Data on the these secondary outcomes were also
collected: ARR of progression to muscle-invasive BCa
during follow-up, and relative risk of severe adverse events
defined by either a modified Clavien grading classification
�2 or as defined in the trial protocol [13]. Summary data
on nonsevere adverse events were also collected and
tabulated.
2.2. Search methods for identification of studies
Electronic searches were carried out using the Medline,
Embase, and Cochrane databases for trials published before
March 2013. The search was assisted by a professional
librarian with extensive experience in searching methodol-
ogy for systematic reviews. A detailed search strategy is
E U R O P E A N U R O L O G Y 6 4 ( 2 0 1 3 ) 4 2 1 – 4 3 0422
presented in Appendix A where the following four concepts
were combined: BCa or therapeutic irrigation, cancer
recurrences or prevention or prophylaxis, antineoplastic
agents, and controlled clinical trials or meta-analysis or
observational.
References from review articles, meta-analyses, and
trials relating to our study topic were reviewed and cross-
referenced to ensure completeness of our literature search.
Conference abstracts from the American and European
urologic association meetings were also searched.
2.3. Data extraction and management
2.3.1. General
Two reviewers (N.P., G.S.K.) performed study selection
(k = 0.92) (Fig. 1). Disagreements were resolved by discus-
sion and consensus. Titles and abstracts were used to screen
for initial study inclusion. Full-text review was carried out
on the remaining papers that matched inclusion/exclusion
criteria. The same reviewers performed all data extraction
including evaluating study characteristics and outcome
data. Disagreements were resolved by consensus. A data
collection form was designed and pilot-tested to ensure
completeness and agreement for the first three studies. If
trials had multiple publications, publications with the
longest follow-up were used and older publications were
accessed to clarify methods if required.
2.3.2. Assessment of risk of bias in included studies
The Cochrane Collaboration’s tool for assessing risk of bias,
which includes selection, performance, attrition, detection,
and reporting bias, was used to assess risk of bias for each
included study [14]. It is specifically designed for assessing
bias in RCTs and addresses sequence generation, allocation
concealment, blinding, handling of incomplete data, and
selective reporting. As per Cochrane guidelines, for a study
to achieve a global low risk score, all key domains (in our
study sequence generation, allocation concealment, and
blinding) must be low risk. If any single domain was
high risk, the study was automatically graded high risk on
the global scale [15].
2.3.3. Measures of treatment effect
Treatment effect was measured using RFI time-to-event
data from Kaplan-Meier curves. Where HR and 95%
confidence intervals (CIs) were not available, they were
approximated using the method of Parmar et al. [16]. ARR
was used to evaluate ERs and disease progression.
2.4. Heterogeneity and reporting bias
The Q test was used to evaluate statistical heterogeneity
( p < 0.10). The I2 statistic was used to assess between-study
heterogeneity’s contribution to overall heterogeneity [17].
Funnel plots were generated to assess the possibility of
publication bias using established methods [18].
2.5. Data synthesis
2.5.1. Primary outcomes
Meta-analysis was performed for prespecified outcomes
and stratified data when sufficient data were available. The
Cochrane Collaboration RevMan (v.5) software was used for
statistical analyses. Acknowledging the clinical heteroge-
neity inherent in our sample with several different study
medications, random-effects models were used for all
meta-analyzed data. Weighting was performed using the
inverse variance method except for one secondary outcome,
disease progression, where Mantel-Haenszel weighting was
used because of its superior ability to handle rare events
[19].
2.5.2. Subgroup analysis
Four a priori subgroups were planned for data stratification
by intervention drug, tumor risk, placebo use in control
group, and continuous bladder irrigation (CBI) use in trial.
[(Fig._1)TD$FIG]
Total citationsn = 4929
Studiesincludedn = 13
Duplicate citationsn = 1878
Full-text reviewn = 36
Unique citationsn = 3051
Excluded followingabstract reviewn = 3015
Excluded followingfull-text review
n = 23
761 – Basic science 680 – Nontrial/review 658 – Non-BCa focused 576 – MIBC 239 – Long-term course IVC 101 – Irrigation nontrial
12 – No control group 4 – Long-term IVC 3 – Oral chemotherapy 2 – Non-RCT 1 – Non-chemotherapy 1 – No early recurrences or RFI outcome available
Fig. 1 – Flow diagram outlining search results and final included and excluded studies. BCa = bladder cancer; MIBC = muscle-invasive bladder cancer;IVC = intravesical chemotherapy; RCT = randomized controlled trial; RFI = recurrence-free interval.
E U R O P E A N U R O L O G Y 6 4 ( 2 0 1 3 ) 4 2 1 – 4 3 0 423
Tumor risk was defined by inclusion criteria where studies
enrolling patients with more than two high-risk inclusion
criteria (high-grade, multiple, recurrent, or tumors >3 cm)
[10] were deemed higher risk. The remaining studies were
deemed lower risk. The presence of CIS was not included in
this definition because CIS was an exclusion criterion for
study involvement, and tumor stage was not included
because no trials included T2 tumors. Because CBI was not
typically described in the papers or RCT protocols, authors
and institutions were contacted via e-mail and telephone to
clarify its use in each trial.
2.6. Quality-of-evidence assessment
Evidence quality was judged using the Grading of Recom-
mendations, Assessment, Development, and Evaluation
(GRADE) system [20]. In this approach, scores for evidence
quality are generated separately for each outcome. For
systematic reviews of RCTs, evidence is initially assumed to
be of high quality. However, scores can be downgraded to
moderate, low, or very low based on the presence of biased
study design, indirectness of evidence, unexplained het-
erogeneity or inconsistency, imprecision, and publication
bias in included studies [21]. GRADEpro v.3.6 software was
used to generate GRADE evidence profiles and tables
summarizing findings.
3. Evidence synthesis
3.1. Literature search
A total of 3051 unique citations were obtained from our
literature search (Fig. 1). After the title and abstract review,
36 studies were examined in detail. Of the 13 included
studies, 9 contained RFI data only, 2 contained ER data only,
and 2 contained both (Table 1). One study was published in
Turkish [32], which was translated with the help of
language translation software. Twenty-three full-text
reviewed publications did not meet the inclusion criteria
(Appendix B).
Appendix C presents the details of quality assessment,
as measured by the Cochrane Collaboration risk-of-bias
tool. Overall, although most trials were free of selective
reporting, few adequately detailed randomization, and only
one trial had adequate blinding of key study personnel and
patients (Fig. 2). Only one trial, Bohle et al. [31], met the
criteria for low overall risk of bias. The remaining trials were
assessed as exhibiting high risk of bias.
A combined 2548 patients were included in all trials
(mean: 196). Six different study drugs were used across the
trials, although 9 of 13 trials (69%) used mitomycin C (MMC)
or epirubicin, both of which are DNA-targeting antitumor
antibiotics. Only four trials (31%) used placebo, and only
three (23%) explicitly detailed CBI use. Although there were
differences in study drugs between trials, patient factors,
tumor characteristics, and study design were similar
enough to justify aggregating data for meta-analysis.
3.2. Effects of interventions
3.2.1. Primary outcome: recurrence-free interval
IVC instillation prolonged RFI by 38% (HR: 0.62; 95% CI,
0.50–0.77; p < 0.001) in those patients receiving interven-
tion within 24 h of TURBT compared with controls (Fig. 3).
Significant ( p < 0.001) statistical between-study heteroge-
neity was present, with 69% of variance secondary to
between-study differences (I2: 69%). The overall RFI
improvement with IVC did not significantly change in a
sensitivity analysis where studies whose HRs were attained
with the Parmar method (HR: 0.58; 95% CI, 0.40–0.83;
p < 0.001) were removed.
Stratification by study drug demonstrated RFI improve-
ment for both MMC (three trials; HR: 0.49; 95% CI,
0.28–0.88; p < 0.001; I2: 82%) and epirubicin (four trials;
Table 1 – Randomized controlled trials included in meta-analysis comparing immediate postoperative intravesical chemotherapy withcontrol
Study Totalno. of
patients
Tumorrisk
Interventiondrug and dose
Placebo CBI Blinding Medianfollow-up
Primaryoutcomemeasure
Oosterlinck et al. [22] 399 Higher risk Epirubicin 80 mg Water 24 h No 2 (mean) RFI
Fujita [23] 90 Higher risk Peplomycin 80 mg None Not specified No 2.25 (mean) RFI
Medical Research
Council report [24]
246 Higher risk Thiotepa 30 mg None Discretion of physician No 8.75 RFI
Tolley et al. [25] 306 Higher risk MMC 40 mg None Discretion of physician No 7 RFI
Solsona et al. [26] 121 Lower risk MMC 30 mg None No No 7.83 RFI and ERs
Rajala et al. [27] 134 Higher risk Epirubicin 100 mg None 2 h
Control only
No 6 RFI
Okamura et al. [28] 170 Higher risk THP-doxorubicin 30 mg None No No 3.4 RFI
El-Ghobashy et al. [29] 63 Lower risk MMC 30mg None Not specified No 3.66 (mean) ERs
Berrum-Svennung
et al. [30]
307 Lower risk Epirubicin 50 mg NS Discretion of physician Partial NR RFI
Gudjonsson et al. [8] 219 Higher risk Epirubicin 80 mg None Discretion of physician No 3.9 RFI
Bohle et al. [31] 248 Higher risk Gemcitabine 2 g NS 20 h Yes 2 RFI
Tatar et al. [32] 43 Higher risk MMC 40 mg NS or
Water
No No 1 ERs
De Nunzio et al. [33] 202 Lower risk MMC 40 mg None 12 h Partial 7.5 RFI and ERs
CBI = continuous bladder irrigation (with saline); ERs = early recurrences; NS = normal saline; RFI = recurrence-free interval.
E U R O P E A N U R O L O G Y 6 4 ( 2 0 1 3 ) 4 2 1 – 4 3 0424
HR: 0.65; 95% CI, 0.55–0.77; p < 0.001; I2: 0%). Differences
in effect size between subgroups was not statistically
significant ( p = 0.38).
Stratification by tumor risk category demonstrated RFI
improvement for both lower risk tumors (three trials; HR:
0.51; 95% CI, 0.28–0.90; p = 0.003; I2: 83%) and higher risk
tumors (eight trials; HR: 0.66; 95% CI, 0.52–0.84; p = 0.006;
I2: 64%). Differences in effect size between subgroups was
not statistically significant ( p = 0.41).
When RFI was stratified by placebo use, trials without
placebo demonstrated a 44% reduction in RFI (HR: 0.56; 95%
CI, 0.41–0.76; p < 0.001; I2: 75%), whereas those that
used placebo demonstrated a 25% reduction in RFI (HR:
0.75; 95% CI, 0.61–0.91; p = 0.004; I2: 4%). Differences in
effect size between subgroups was not statistically signifi-
cant ( p = 0.12).
Data regarding CBI use were obtained for 11 of the
13 trials (Table 1). CBI of widely varying duration was used
for both intervention and control arms in three trials, only in
controls in one trial, according to the discretion of treating
physicians in four trials, and not used in three trials.
Information on CBI use from two trials could not be
obtained despite several attempts to contact authors and
institutions. Meaningful calculations of the impact of CBI on
recurrence were not possible due to the clinical heteroge-
neity of the data.
All studies with RFI outcome data were plotted on a
funnel plot comparing effect size and measure of precision
of the effect size (Fig. 4). Four studies with small sample size
and large positive effect were published. There was a
theoretical absence of studies published with small sample
size and large negative effect, suggesting the possibility of
publication bias.
[(Fig._3)TD$FIG]
Fig. 3 – Forest plot comparing recurrence-free interval in patients receiving intravesical chemotherapy versus controls. CI = confidence interval;IV = inverse variance; SE = standard error.
[(Fig._2)TD$FIG]
Fig. 2 – Risk-of-bias graph: reviews of authors’ judgments about each risk-of-bias item presented as percentages across all included studies.
[(Fig._4)TD$FIG]
Fig. 4 – Funnel plot examining the possibility of publication bias. The plotwas created by comparing the variance with effect size in publicationscomparing recurrence-free interval of patients receiving intravesicalchemotherapy versus controls. SE = standard error.
E U R O P E A N U R O L O G Y 6 4 ( 2 0 1 3 ) 4 2 1 – 4 3 0 425
3.2.2. Primary outcome: early recurrences
ERs were 12% less likely in the intervention population
(ARR: 0.12; 95% CI, �0.18 to �0.06; p < 0.001; I2: 0%)
(Fig. 5). Thus nine patients would need to be treated with
IVC to prevent one BCa recurrence within the first year
following treatment (NNT: 9; 95% CI, 6–17 patients). Due to
the small number of trials reporting ERs, subgroup analysis
and publication bias assessment were not possible.
3.2.3. Secondary outcome: bladder cancer progression
Only four studies reported BCa progression (Fig. 6). This was
a rare event, occurring in only 3.0% of patients receiving
[(Fig._5)TD$FIG]
Fig. 5 – Forest plot comparing early recurrences (within 1 yr) between patients receiving immediate intravesical chemotherapy after transurethralresection of bladder tumor versus controls. CI = confidence interval; IV = inverse variance; SE = standard error.
[(Fig._6)TD$FIG]
Fig. 6 – Forest plot comparing bladder cancer progression (to muscle invasion) between patients receiving intravesical chemotherapy after transurethralresection of bladder tumor versus controls. CI = confidence interval; IV = inverse variance; SE = standard error.
Table 2 – Summary of nonserious adverse events reported in trials examining the effect of immediate postoperative intravesicalchemotherapy on non–muscle-invasive bladder cancer recurrences
Study Adverseevents
reported
Interventiondrug and dose
Mild cystitis,frequency,
urgency
Mildhematuria
Skinirritation,
rash
Other
Oosterlinck et al. [22] Yes Epirubicin 80 mg 11.7% intervention;
1.9% control
– 1.0%
intervention
Nine other nonserious complications
(7 intervention, 2 control)
Fujita [23] Yes Peplomycin 80 mg – – – ‘‘No patient developed acute bladder
irritation or chronic bladder contraction’’
Medical Research
Council report [24]
Yes Thiotepa 30 mg 2.5% intervention – 0.5%
intervention
One patient with widespread edema in
the thiotepa group
Tolley et al. [25] Yes MMC 40 mg 0.7% intervention – – –
Solsona et al. [26] Yes MMC 30 mg 3.5% intervention;
1.5% control
– – –
Rajala et al. [27] No Epirubicin 100 mg – – – –
Okamura et al. [28] Yes THP 30 mg 10.4% overall 5.2%
overall
– Only overall adverse events reported
El-Ghobashy et al. [29] Yes MMC 30 mg 6.5% intervention;
3.1% control
– – –
Berrum-Svennung
et al. [30]
No Epirubicin 50 mg – – – –
Gudjonsson et al. [8] No Epirubicin 80 mg – – – –
Bohle et al. [31] Yes Gemcitabine 2 g – – – ‘‘Adverse events possibly attributed to
intervention 11/166, placebo 6/162 all
nonserious’’
Tatar et al. [32] No MMC 40 mg – – – –
De Nunzio et al. [33] Yes MMC 40 mg 9.3% intervention – – –
MMC = mitomycin C.
E U R O P E A N U R O L O G Y 6 4 ( 2 0 1 3 ) 4 2 1 – 4 3 0426
Table 3 – Quality of evidence assessment and summary of findings using the GRADE system
Question: Should immediate post-TURBT intravesical chemotherapy be used for non–muscle-invasive bladder cancer?
Quality assessment Summary of findings
Participants(Studies)Follow-up
Risk of bias Inconsistency Indirectness Imprecision Publication bias Overall qualityof evidence
Relative effect(95% CI)
Anticipated absolute effects
Risk withcontrol
Risk differencewith immediate
post-TURBT intravesicalchemotherapy (95% CI)
Recurrence-free interval (assessed with surveillance cystoscopy and confirmed with biopsy)
2442
(11 studies)
2–8.75 yr
Seriousa Seriousb No serious
indirectness
No serious
imprecision
Reporting bias
strongly suspectedc
�O O O
VERY LOWa,b,c
due to risk of bias,
inconsistency,
publication bias
HR: 0.62
(0.5–0.77)
599 RFIs/1000d 166 fewer RFIs/1000
(from 94 fewer to
232 fewer)
Early recurrences within 1 yr (assessed with surveillance cystoscopy and confirmed with biopsy)
429
(4 studies)
1–7.5 yr
Seriouse No serious
inconsistency
No serious
indirectness
Seriousf Undetected ��O O
LOWe,f
due to risk of
bias, imprecision
See commenth 211 ERs/1000 124 fewer ERs/1000
(from 59 fewer to
179 fewer)
Progression to T2 bladder cancer (assessed with surveillance cystoscopy and confirmed with biopsy)
831
(4 studies)
2–7.5 yr
Seriousa No serious
inconsistency
Seriousg Seriousf Undetected �O O O
VERY LOWa,f,g
due to risk of bias,
indirectness,
imprecision
See commenth 19/1000 11 more/1000
(from 10 fewer to
30 more)
Serious adverse events (assessed with modified Clavien grading classification �2 or as defined in trial protocol)
0
(9 studies)
– – – – – No GRADE applied
due to zero events
– – –
CI = confidence interval; ERs = early recurrences; GRADE = Grading of Recommendations, Assessment, Development, and Evaluation; HR = hazard ratio; RFIs = recurrence-free intervals; TURBT = transurethral resection of
bladder tumor.a Risk of bias in all trials except Bohle et al. [31] was ‘‘high’’ due to lack of blinding and unclear randomization.b Significant statistical heterogeneity and high I2 (69%).c See publication bias plot (Fig. 4). Concern that studies with large negative effect were not published.d Assumed baseline event rate for control group is approximated using data from Tolley et al. [25] (59.9%) because it approximates the average across trials and is from a trial with a large sample size using a common
intravesical chemotherapy (mitomycin C).e Risk of bias for all included studies was ‘‘high’’ according to Cochrane risk of bias tool. Studies lacked blinding and had unclear randomization.f Small sample size and number of events.g Progression to T2 bladder cancer outcome was not the primary outcome measure for any of the included studies.h Risks were calculated from pooled absolute risk reductions.
EU
RO
PE
AN
UR
OL
OG
Y6
4(
20
13
)4
21
–4
30
42
7
chemotherapy (12 of 406) and 1.9% of controls (8 of 425)
with no statistically significant difference ( p = 0.28).
3.2.4. Secondary outcome: adverse events
Adverse event data were reported in nine studies. There
were no documented serious adverse events in any
study. Table 2 summarizes the nonserious adverse event
data.
3.3. Quality-of-evidence review
Results of the GRADE system quality-of-evidence review are
presented in Table 3 for all primary and secondary outcome
measures. No grade was assigned to serious adverse events
because none were reported.
4. Conclusions
This systematic review and meta-analysis with 13 studies
and 2548 patients expands on the previous meta-analysis in
2004 [5] composed of 7 studies and 1476 patients, and it
differs in several ways.
First, we performed a thorough risk-of-bias evaluation
for all included studies. Second, random-effects models
were used because trials with multiple different study
drugs were combined, and there was unlikely one true
effect to be identified. Third, the GRADE system, adopted by
the Cochrane Collaboration [21] and the suggested manner
in which to generate more transparent and structured
reviews [34], was used to grade the quality of evidence in
this systematic review. Interestingly, our findings are
similar to the previous meta-analysis [5]. This systematic
review suggests that immediate postoperative IVC instilla-
tion in patients with NMIBC increases RFI and reduces ERs
with minimal morbidity.
The methods of our study differ from a very recent
meta-analysis by Abern et al. also supporting the benefit of
postoperative IVC instillation [35] where 18 trials were
synthesized and the effects of tumor risk factors were
calculated using meta-regression. Risk-of-bias and quality-
of-evidence assessment were important additions in our
analysis. We also deliberately elected to use a time-to-event
end point (RFI) as a main outcome measure because it
addresses the temporal sequence of recurrences. For patients
with NMIBC, extending the time from TURBT to recurrence is
vital. Using a time-to-event metric is particularly important in
this question because the RCTs available had vastly different
median durations of follow-up. Indeed, by simply combining
all events from all trials (as would be the case if an aggregated
odds ratio were calculated), a recurrence at 6 mo after
TURBT would be treated identically to a recurrence 6 yr after
TURBT.
We performed several a priori subgroup analyses to
examine whether the effect of IVC differed in various
clinical situations. The RFI-reducing effect of IVC persisted
regardless of tumor risk (lower or higher) or drug used (only
MMC and epirubicin were examined in enough studies to be
included in subgroup analysis) without statistically signifi-
cant differences between effects.
The final subgroup analysis examined whether studies
using water or saline placebo intravesical instillation had an
impact on RFI. We suspected that placebo instillation could
reduce recurrences via several mechanisms. The placebo
effect has been well documented in sham procedures [36].
Also, the instillation of any agent into the bladder may
theoretically decrease tumor recurrence via mechanical
lavage of circulating tumor cells, or if the agent is hypotonic,
tumor cell lysis may ensue [37]. There is observational
study data demonstrating equal recurrence rates between
patients treated with MMC versus CBI with saline [38].
Finally placebo use may simply reflect better quality studies
that have been shown to be associated with reduced effect
size [39]. However, the use of placebo did not demonstrate a
statistically significant difference in subgroup analysis.
We also attempted to evaluate whether CBI after TURBT
could affect tumor recurrence. We hypothesized that CBI
may play a role in reducing tumor recurrence by providing
an extended period of mechanical lavage of tumor cells after
resection. CBI is sometimes used after transurethral
operations to prevent blood clotting and allow for adequate
hemostasis and catheter drainage. One unpublished study
in which 866 patients were randomized to CBI versus no CBI
following TURBT demonstrated an improved RFI for
patients in the CBI arm [40]. Of the 13 trials included in
this review, only 3 trials mandated CBI after TURBT, and
each was for a varying duration from 2 to 24 h. None of the
other publications described whether CBI was used or not.
By contacting authors and institutions, we learned that CBI
use varied, and it was often left to the discretion of the
treating urologist. Thus the high degree of clinical
heterogeneity in CBI use prohibited meta-analysis of the
data.
Despite the evidence that IVC reduces recurrences,
which is reinforced by our study, many practitioners do
not use this intervention for their patients. In a recent
survey of 259 practicing urologists, 66% did not use
postoperative chemotherapy for their patients [41]. The
most commonly cited reasons for limited use were
increased cost, challenge of administering chemotherapy
in the operating or recovery room, possibility of serious side
effects, and the belief that decreasing small superficial BCa
recurrences is not clinically important. Additionally, the
strength of the primary studies has been questioned,
particularly because it has been demonstrated that the
benefit from IVC was driven by RCTs with small sample size
and large effect [9]. However, despite these criticisms, both
the American and European urologic societies support post-
TURBT IVC for all suspected NMIBC [10,11].
IVC administration appears safe and relatively nontoxic.
There were no serious adverse events reported in the
studies included in our meta-analysis. However, in a study
using 50 mg epirubicin, not included here because it did not
contain time-to-event data or data on ERs, one patient
experienced permanent bladder contraction secondary to
IVC [42].
The quality of evidence for each outcome in this study as
judged using the GRADE system ranged from low to very
low. Quality scores for all outcomes were downgraded
E U R O P E A N U R O L O G Y 6 4 ( 2 0 1 3 ) 4 2 1 – 4 3 0428
because data for this meta-analysis were extracted from
studies at high risk of bias. In most of the studies, the
urologist and patients were not blinded and placebo was
not used, which may cause bias toward improved outcomes
in patients receiving the study drug. The RFI outcome was
further downgraded due to inconsistent results (significant
heterogeneity) and potential for publication bias illustrated
by the lack of studies published with small sample size
and negative effect. Further downgrading of the ERs and
progression to T2 outcomes was secondary to imprecision
caused by small sample size. Finally, the progression to T2
outcome suffered from indirectness because it was not a
primary outcome in most included studies. Due to the low
evidence quality, it may not be suitable to rely on these
results to guide clinical decisions.
The report by Bohle et al. [31] was the only study
identified with a low overall risk of bias. Interestingly, in
their trial, IVC using gemcitabine did not reduce NMIBC
recurrences.
This study has several limitations. There was a high
degree of heterogeneity in the studies included in this meta-
analysis. For one primary outcome, RFI, between-study
heterogeneity accounted for 69% of the overall heterogene-
ity beyond chance alone. High between-study heterogene-
ity persisted despite stratification and subgroup analyses.
Unmeasured items that could not be accounted for,
including variation in surgical technique between sites,
patient comorbidities, and age, may be driving the
heterogeneity. Additional limitations of this study include
the lack of individual patient data and the likely variation in
surgical quality across studies. Jancke et al. described the
association between incomplete tumor resection and local
NMIBC recurrences [43], which may be the case for some
studies included in the meta-analysis. However, despite
these limitations, we believe this study carefully evaluates
and fairly represents the most current evidence for
immediate postoperative IVC for low- and intermediate-
risk NMIBC.
In summary, the practice of immediate postoperative
IVC in NMIBC has polarized health care providers due to
challenges in drug administration and conflicting primary
data [6,8]. The implications of our study are relevant to both
patients and health systems worldwide given the high costs
associated with this disease [1]. This meta-analysis con-
firms, with updated data and contemporary methodology,
that IVC reduces NMIBC recurrences when given immedi-
ately following TURBT with minimal adverse events.
Subgroup analyses suggest that this effect persists for
several study drugs, risk groups, and whether or not placebo
was used in each trial. However, due to the low quality of
evidence, we still suggest that a well-designed RCT with
proper blinding and placebo be performed with one of the
more commonly used agents.
Author contributions: Nathan Perlis had full access to all the data in the
study and takes responsibility for the integrity of the data and the
accuracy of the data analysis.
Study concept and design: Perlis, Kulkarni, Finelli, Fleshner, Zlotta.
Acquisition of data: Perlis, Kulkarni.
Analysis and interpretation of data: Perlis, Kulkarni, Beyene.
Drafting of the manuscript: Perlis, Kulkarni,
Critical revision of the manuscript for important intellectual content:
Kulkarni, Beyene, Zlotta.
Statistical analysis: Perlis, Beyene.
Obtaining funding: None.
Administrative, technical, or material support: None.
Supervision: Kulkarni, Zlotta.
Other (specify): None.
Financial disclosures: Nathan Perlis certifies that all conflicts of interest,
including specific financial interests and relationships and affiliations
relevant to the subject matter or materials discussed in the manuscript
(eg, employment/affiliation, grants or funding, consultancies, honoraria,
stock ownership or options, expert testimony, royalties, or patents filed,
received, or pending), are the following: None.
Funding/Support and role of the sponsor: None.
Appendix A. Supplementary data
Supplementary data associated with this article can be
found, in the online version, at http://dx.doi.org/10.1016/
j.eururo.2013.06.009.
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