Update on the Surgical Trial in Lobar Intracerebral Haemorrhage (STICH II): statistical analysis plan
© Gregson et al.; licensee BioMed Central Ltd. 2012
Received: 18 July 2012
Accepted: 29 October 2012
Published: 21 November 2012
Previous studies had suggested that the outcome for patients with spontaneous lobar intracerebral haemorrhage (ICH) and no intraventricular haemorrhage (IVH) might be improved with early evacuation of the haematoma. The Surgical Trial in Lobar Intracerebral Haemorrhage (STICH II) set out to establish whether a policy of earlier surgical evacuation of the haematoma in selected patients with spontaneous lobar ICH would improve outcome compared to a policy of initial conservative treatment. It is an international, multi-centre, prospective randomised parallel group trial of early surgery in patients with spontaneous lobar ICH. Outcome is measured at six months via a postal questionnaire.
Recruitment to the study began on 27 November 2006 and closed on 15 August 2012 by which time 601 patients had been recruited. The protocol was published in Trials (http://www.trialsjournal.com/content/12/1/124/). This update presents the analysis plan for the study without reference to the unblinded data. The trial data will not be unblinded until after follow-up is completed in early 2013. The main trial results will be presented in spring 2013 with the aim to publish in a peer-reviewed journal at the same time.
The data from the trial will provide evidence on the benefits and risks of early surgery in patients with lobar ICH.
The Surgical Trial in Lobar Intracerebral Haemorrhage (STICH II) aims to establish whether a policy of earlier surgical evacuation of the haematoma in selected patients with spontaneous lobar intracerebral haemorrhage (ICH) will improve outcome compared to a policy of initial conservative treatment. The trial will also help to better define the indications for early surgery.
This is an international multi-centre parallel group trial with patients randomised to receive either ‘early surgery’ (ES) or ‘initial conservative treatment’ (ICT). Outcome is measured at six months by postal questionnaire to the patients.
Eligible patients have evidence of a spontaneous lobar ICH on computed tomography (CT) scan (1 cm or less from the cortical surface of the brain) with a volume of between 10 and 100 ml, are within 48 hours of ictus, have a best motor score on the Glasgow Coma Score (GCS) of five or six and best eye score of two or more. They are not eligible if there is clear evidence that the haemorrhage is due to an aneurysm or angiographically proven arteriovenous malformation, that it is secondary to tumour or trauma, involves the basal ganglia, thalamic, cerebellar or brainstem regions, or if there is any intraventricular blood. Patients should also not have any severe pre-existing physical or mental disability or severe co-morbidity that might interfere with assessment of outcome. They should be able to have surgery within 12 hours if randomised to that group.
All patients who are randomised and have outcome measured will be included in the analysis. Patients who withdraw consent from the study will not be included. The primary analysis will be ‘intention to treat’ with data analysed according to the treatment group to which the patient was randomised. This update to the published protocol  provides details of the statistical analysis plan for STICH II.
Background to the statistical analysis of STICH II
Results from similar trials
Further detailed analysis of data from the STICH study
In order to plan data analysis of STICH II, it is useful to examine the data collected in the first STICH study  for cases that would have been eligible for STICH II under the present inclusion criteria.
In particular, the haematoma should be located in the lobar region with no haematoma in the basal ganglia or thalamus or in the ventricles and no more than 1 cm from the cortex surface. The size of the haematoma should be between 10 and 100 ml. The patient’s GCS motor component at randomisation should be five or six and the eye component two or more. The patient should be within 48 hours of ictus.
For values of the size and location of blood in the brain, we have available to us measures reported by the local investigator at the time of randomisation and also the assessments made by the central examiners from the measurements made on the randomisation CT scan supplied to us. Since it is the local investigator who decides whether a patient is eligible or not, for this analysis the measurements reported on the randomisation form will be used. However, presence of IVH was not reported at randomisation so that information will be taken from the central assessment.
This selection provides 157 patients who had all the inclusion criteria (78 randomised to ES and 79 to ICT). Outcome at six months is available for 147 of these patients (74 ES, 73 ICT). Of the ten lost patients, no follow-up at all was obtained for six patients and four patients were known to be alive at six months but died before follow-up could be obtained so disability at six months is unknown. There were a few discrepancies between the randomisation assessment and the central assessment of haematoma characteristics. The depth from the cortical surface exceeded 1 cm in four cases (maximum 1.8 cm). The volume was less than 10 ml in one case (8.2 ml) and more than 100 ml in four cases (101.2, 101.7, 103.2 and 137.3).
Dichotomising the five-point Glasgow Outcome Scale (GOS) at the usual point (good recovery (GR), moderate disability (MD) versus severe disability (SD), vegetative (V), dead (D)) gave 37% favourable outcome overall with 45% in the ES group and 30% in the ICT group (Fisher’s exact P = 0.089, Pearson’s chi-squared = 0.070). Using the prognostic-based outcome reported in the Lancet paper  gives 41% favourable outcome overall (49% in the ES group and 33% in the ICT group).
For the 147 patients with outcome assessment, the two treatment groups were well matched on the usual predictive variables of age <65 (42% ES and 42% ICT) and volume >50 ml (31% ES and 32% ICT), but for GCS 13 to 15 (70% ES and 63% ICT) and whether the patient was randomised within 12 hours (24% ES and 36% ICT), there was evidence of some differences.
In the surgery group, 52 patients (70%) had surgery within 12 hours, 2 patients did not receive surgery and 8 had surgery after 24 hours (26 to 49). In the initial conservative group, 25 (34%) had surgery, 8 within 12 hours of randomisation and 13 had surgery after 24 hours.
Sample size in STICH II
In the protocol for STICH II, it is stated that with a 37% favourable outcome from conservative treatment a sample size of 566 would be required to show a 12% benefit from surgery (2P <0.05) with 80% power. A sample size of 600 was therefore proposed to allow for withdrawals and crossovers.
Randomisation procedures in STICH II
Patients are allocated according to a minimisation algorithm based on age (three bands: <60, 60 to 69, 70+) and neurological deficit in the worst affected arm or leg (three bands: normal, weak, paralysed) with a random component such that there is a 20% chance of the allocation being reversed. Patients are stratified by country group and planned operation (two bands: craniotomy, other). Sites are grouped by country (if we expected many sites within a country to be included) or a country group (if we expected only one site in the country). Country groups were defined, as they arose, according to geographic location.
Analysis statement in protocol for STICH II
The analysis statement in the protocol says: analysis will be on an ‘intention to treat’ basis. The primary analysis will be a simple categorical frequency comparison using the chi-squared test for prognosis-based [4, 5] favourable and unfavourable outcomes at six months. Patients with a good prognosis will be categorised as having a favourable outcome if they achieve GR or MD on the GOS. Patients with a poor prognosis will be categorised as having a favourable outcome if they achieve GR, MD or upper SD on the Glasgow Outcome Scale-Extended (GOSE). Logistic regression analysis will be undertaken to adjust for covariates. Secondary outcomes will also be analysed using the prognosis-based method as specified in STICH .
Statistics that will be reported
For categorical variables, the number and percentage in each group will be reported. Percentages will be reported to no decimal places. For continuous variables the median, quartiles, maximum and minimum will be reported. Where P values are reported these will be to three decimal places or at P <0.0001. The presence of missing data will be reported.
Methods for statistical analyses to be reported in STICH II
Evaluation of demographics and baseline characteristics
Baseline characteristics will be reported separated by treatment. The first table will include gender, age, pre-ICH mobility, pre-ICH Rankin, time between ictus and randomisation, GCS, neurological deficit in worst arm, worst leg, and worst limb, speech, whether receiving any anticoagulation or thrombolytic treatment prior to ictus, past medical history and prognostic score. Prognostic score will be derived as reported in STICH (10 x GCS – age (years) – 0.64 x volume (ml)) with a cut point of 27.672 to differentiate between patients with a good prognosis (score greater than cut point) and those with a poor prognosis.
The second table will include details of site of haematoma, volume and depth from the site assessments plus those and other measures from the central assessment.
Evaluation of treatment compliance and exposure
Crossovers will be reported. The third table will include details of surgery for both groups including time from ictus to surgery, and number and percentage operated within 12 hours of ictus, time from randomisation to surgery, method, any additional procedures, and status prior to evacuation, whether sedated, GCS, and neurological status of worst arm, leg and speech. Reasons for crossover will be reported. Amount of blood removed during operation will be reported (as assessed by differences in blood volume on randomisation scan and on the five-day CT scan).
Outcomes will be reported as odds ratios with 95% confidence interval reported to two decimal places and P values to three decimal places. Absolute benefits with 95% confidence intervals to one decimal place will also be reported.
The primary outcome analysis will be a simple categorical frequency comparison using the chi-squared test for prognosis-based favourable and unfavourable outcomes on the eight-point GOS at six months. GOS will be computed from the answers to the 14 questions as per the paper of Wilson, Edwards et al.  Where a response to a question is missing, the assessment will be made using the responses to the other questions. The allocation of outcome assessment will be made prior to unblinding the treatment assignment.
Logistic regression analysis will be undertaken to adjust for covariates age, GCS, volume of haematoma and neurological deficit.
Six-month outcome assessment may actually be made any time after five months. Where it is very late, the respondents are asked to answer the questions for an assessment of the capabilities of the patient at the six-month point. If a patient dies after six months but prior to the six-month outcome being completed and it is impossible to obtain an assessment of the patient’s abilities at six months, the patient will be excluded from analysis of GOS.
Secondary outcome analysis will include Kaplan-Meier survival curve with log-rank test, mortality at six months, a prognosis-based modified Rankin score, reporting of the eight-point GOS, Rankin and EuroQol broken down by randomised treatment group.
An analysis based on a proportional odds model will be undertaken as a sensitivity analysis. In addition, sensitivity analyses will be undertaken based on imputation of missing outcome data.
Odds ratios and 95% confidence intervals will be reported for the following subgroups: age (two bands using median split: <65, >=65), volume of haematoma (using median split <= 35 ml, >35 ml), GCS (8 to 12, 13 to 15), time from ictus to randomisation (using median split <21 hours, >=21 hours), severity of neurological deficit - worse limb (normal, weak, paralysed), planned method of haematoma removal (craniotomy, other). Interaction tests will be undertaken and relevant P values will be reported.
In addition, odds ratios will be reported by country group and by whether the patients had been receiving anticoagulant treatment prior to the haemorrhage.
Per protocol (12 hours) - only patients who received the allocated treatment within 12 hours will be included in this analysis. ES patients will have received surgery within 12 hours or died within 12 hours. ICT patients will not have received surgery within 12 hours.
Per protocol (surgery versus conservative) - only patients who received the allocated treatment will be included in this analysis. ES patients will have received surgery within 12 hours. ICT patients will not have received surgery within 48 hours.
In separate papers, the analysis of the CT scans will be reported. Each CT scan will be read by two independent blinded readers: a neuroradiologist and a neurosurgeon. They are not informed as to whether the scan is a diagnostic scan or a five-day scan and the scans are coded such that they cannot link two scans for one patient. Although the readers will be able to identify if an operation has been undertaken, they will not know which group the patient was randomised to. They will report the location and size of the haematoma, the presence of blood in the ventricles, any midline shift or evidence of other pathology. The inter-rater reliability will be reported. Where there is evidence of disagreement, a third reader will assess the scan. Percentage change in volume of haematoma between the two scans will be compared with outcome according to volume of haematoma on the diagnostic scan.
Incorrect randomisation. There have been a couple of incidences when there have been problems with randomisation. On several occasions, the database manager was given information that the patient had been randomised to one treatment but the investigator had been told the other treatment by the randomisation service. If the investigator acted on the information from the randomisation service this was correct. If the investigator acted on information from the database manager then this was taken as correct and the randomisation service was asked to edit their database. This was a problem created by the randomisation service in Aberdeen, which was identified after a six-month period and affected three patients.
Treatment allocation not heard. On seven occasions the investigator reported that they did not hear the treatment during the phone call (the phone cut out). He/she then went through the system again resulting in the patient being randomised twice. The investigator then used the information from the second call. Sometimes this was the same and sometimes different. If this happened during a working day the database manager immediately contacted the site and asked them to follow the initial allocation. If it was not possible to make this contact immediately then the second allocation was used. In both cases, the randomisation service was contacted to ensure the correct minimisation algorithm was maintained. This occurrence was not related to site.
Missing data. Missing data are rare because sites are contacted to ensure that all data collected by two weeks is available. Sometimes a randomisation CT was not obtained because the patient took it home with them before it was copied or it had been done at an outlying hospital and a copy could not be obtained. For these cases, it will not be possible to estimate change in volume of the haematoma by treatment as estimated by blinded raters. Missing outcome information has been addressed above.
Protocol variations. Some patients may have been recruited who were later found to have been ineligible (central assessment of the CT scan may identify the haematoma as being outside the eligible volume or there might be evidence of blood in the ventricles or of a bleed involving deeper structures, or caused by other mechanisms). These will be detailed but included in all analyses as if appropriately recruited.
Discussion and timetable
Patients were recruited to the trial between 27 November 2006 and 15 August 2012. In total, 601 patients were recruited. Follow-up of recruited patients will continue through 2012 and into 2013. The trial data will be unblinded in early 2013 once data collection is complete and the dataset is closed. The main trial results will be presented in the spring of 2013. The aim will be to publish the results at the same time or soon after.
List of all registered recruiting collaborating centres
ARMENIA - Yerevan State Medical University, Dr Ruben V Fanarjyan
AUSTRALIA - Royal Melbourne Hospital, Prof Stephen Davis
AUSTRIA - Rudolfstiftung Hospital, Vienna, Dr Günther Kleinpeter
Medical University of Vienna, Prof Andreas Gruber
CANADA - University of Alberta Hospital, Edmonton, Dr Max Findlay
CHINA - Tianjin Medical University General Hospital, Prof Shuyuan Yue
Beijing Tiantan Hospital, Dr Yuanli Zhao
Huashan Hospital, Fudan University, Shanghai, Prof Dr Ying Mao
CZECH REPUBLIC - Central Military Hospital, Prague, Prof Vladimir Benes
Fakultni Nemocnice, Ostrava, Dr Tomas Krejci
University Hospital, Brno, Prof Martin Smrcka
St. Anne's University Hospital, Brno, Prof Dr Pavel Cejpak
Fakultni Nemocnice, Olomouc, Prof Miroslav Vaverka
Regional Hospital, Liberec, Dr Pavel Buchvald
EGYPT - Mansoura International Hospital, Dr Abd-Elhafiz Shehab Eldien
Zagazig University Hospital, Dr Mohamed Barakat
Alexandria University Hospital, Prof Osama Abdelaziz
GEORGIA - State Medical University Clinic, Tbilisi, Prof Alexander Gvelesiani
GERMANY - Klinik fur Neurochirurgie, Magdeburg University, Prof Dr Raimund Firsching
Clemens Hospital, Munster, Prof Dr Abolghassem Sepehrnia
Universitatsklinikum Erlangen, Prof Dr Michael Buchfelder
Klinikum Amberg, Dr Andrea Kleindienst
Heinrich Heine University, Duesseldorf, Dr Daniel Haenggi
University Hospital Heidelberg, Dr Karl Kiening
University Clinic, Munster, Prof Walter Stummer
Klinikum Kassel, Prof Dr Wolfgang Deinsberger
Ernst Moritz Arndt University, Greifswald, Prof Dr W S Schroeder
University Schleswig-Holstein, Lubeck, Dr Georg Nowak
Helios Klinikum Berlin Buch, Prof Dr Jurgen Kiwit
Neurochirurgische Klinik, Dessau, Dr Kazimierz Sadowy
Universitatsklinikum des Saarlandes, Prof Wolf-Ingo Steudel
Dr. Horst Schmidt Kliniken, Wiesbaden, Prof Gerhard Hamman
Klinikum Saarbrucken, Winterberg, Dr S Thomas
Charite - University Medicine, Berlin, Prof Eric Juettler
Universitatsklinikum Jena, Dr Albercht Waschke
Asklepios Klinik Altona, Prof Dr Uwe Kehler
Diakonieklinikum, Jun-Stilling Hospital, Siegen, Dr Veit Braun
GREECE - Ippokration General Hospital, Aristotle University, Thessaloniki, Prof Philippos Tstitsopoulos
Evangelismos Hospital, Athens, Mr George Stranjalis
AHEPA General Hospital, Aristotle University, Thessaloniki, Dr Athanasios Spiliotopoulos
HUNGARY - Pecs University Hospital, Dr Andras Buki
Borsod County and University Teaching Hospital, Dr Jozsef Dobai
INDIA - All India Institute of Medical Sciences, New Delhi, Dr P Sarat Chandra
BGS Global Hospital, Bangalore, Dr Shailesh Rao
Christian Medical College and Hospital, Ludhiana, Dr Sarvpreet Singh Grewal
National Neurosciences Centre, Kolkata, Dr K Sridhar
Care Hospital, Visakhapatnam, Dr V P Ramana
Care Hospitals Institute of Neurological Sciences, Hyderabad, Dr T V R K Murthy
Kerala Institute of Medical Sciences, Dr Moni Vinod
Acharya Vinoba Bhave Rural Hospital, Maharashtra, Dr Anand Kakani
Kamineni Hospital, Hyderabad, Dr Subodh Raju
Amri Hospital, Dhakuria, Prof R N Bhattacharya
MM Institute of Medical Sciences and Research, Haryana, Prof Amit Agrawal
Sree Chitra Tirunal Institute for Medical Sciences and Technology, Trivandrum, Dr Suresh Nair
National Institute of Mental Health and Neuro Sciences, Bangalore, Dr B Indira Devi
ISRAEL - Rambam Hospital, Haifa, Dr Leon Levi
Sheba Medical Center, Dr Sagi Harnof
ITALY - University Sapienza, Rome, Prof Robert Delfini
JAPAN - Kanto Medical Center, NTT East Co. Tokyo, Dr Akio Morita
Hirosaki University School of Medicine, Professor Norihito Shimamura
LATVIA - Clinical University Hospital, Gailezers, Riga, Dr Kaspars Auslands
Pauls Stradins Clinical University Hospital, Riga, Prof Egils Valeinis
LITHUANIA - Klaipeda University Hospital, Prof Antanas Gvazdaitis
Kaunas University Hospital, Dr Antanas Gvazdaitis
MACEDONIA - Clinical Center, Skopje, Prof Dr Kiril Lozance
MALAYSIA - Universiti Sains Malaysia, Kubang Kieran, Prof Dr Jafri Malin
Hospital Sultanah Aminah, Johor Bahru, Dr Noor Azman Abdul Rahman
MEXICO - Instituto Nacional de Neurologia y Neurochirugia, Tlalpan, Dr Samuel Romero Vargas
Hospital Civil de Guadalajara, Dr Jose Luis Ruiz-Sandoval
MOLDOVA - National Practical and Scientific Centre of Emergency Medicine, Chisinau, Prof Stanislaw Groppa
NEPAL - B. P. Koirala Institute of Health Sciences, Dharan, Dr Yam Bahadur Roka
B & B Hospital, Gwarko, Lalitpur, Dr Krishna Sharma
NORWAY - St Olavs Hospital, Trondheim University Hospital, Dr Sozaburo Hara
PAKISTAN - Lahore General Hospital, Dr Khalid Mahmood
NW General Hospital and Research Centre, Peshawar, Prof Tariq Khan
POLAND - Poznan University of Medical Sciences, Prof Dr Stanislaw Nowak
University Medical School, Bialystok, Prof Zenon Mariak
ROMANIA - Cluj County Emergency Hospital, Cluj-Napoca, Prof Ioan Stefan Florian
Country Hospital, Timisoara, Dr Horia Ples
RUSSIA - Novosibirsk Medical University, Prof Alex Krivoshapkin
SAUDI ARABIA - King Khalid University Hospital, Riyadh, Dr Essam A Elgamal
SINGAPORE - National University Hospital, Dr Chou Ning
SOUTH AFRICA - Steve Biko Academic Hospital, Pretoria, Professor Sam Mokgokong
SOUTH KOREA - National Medical Center, Seoul, Prof Dae Hee Han
SPAIN - Hospital Universitario 'Marques de Valdecilla', Santander, Prof Alfonso Vazquez-Barquero
Hospital Universitario Virgen de las Nieves, Granada, Dr Majed J Katati
Hospital Clinico Universitario, Valladolid, Dr Rosario Sarabia
Hospital de Cruces, Bilbao, Prof Jesus Garibi Undabarra
Germans Trias I Pujol University Hospital, Barcelona, Dr Carlos Alonso
Hospital Universitario Rio Hortego, Valladolid, Dr Rosario Sarabia
University Son Espases, Majorca, Dr Javier Ibanez
University Hospital Murcia, Dr Marcelo Galarza
SRI LANKA - National Hospital of Sri Lanka, Colombo, Dr H D S Kularathne
SWEDEN - Akademiska Sjukhuset, Uppsala, Prof Per Enblad
TAIWAN - Taipei Medical University Hospital, Dr Kuo-Hsing Liao
THE NETHERLANDS - University Medical Centre, Groningen, Dr Gert-Jan Luijckx
TURKEY - University of Istanbul, Prof Orhan Barlas
UK - Ninewells Hospital, Dundee, Professor M Sam Eljamel
Radcliffe Infirmary, Oxford, Mr Richard Kerr
Hurstwood Park, Haywards Heath, Mr Giles Critchley
James Cook University Hospital, Middlesbrough, Mr Roger Strachan
The National Hospital for Neurology and Neurosurgery, London, Mr Laurence Watkins
Aberdeen Royal Infirmary, Dr Pragnesh Bhatt
Southampton University Hospital, Mr Antonio Belli, Mr Diederik Bulters
Addenbrooke's Hospital, Cambridge, Mr Peter Kirkpatrick
Newcastle General Hospital and Royal Victoria Infirmary, Newcastle, Mr John Crossman
Leeds General Infirmary, Mr Jake Timothy
Morriston Hospital, Swansea, Mr Robert Redfern
Salford Royal Infirmary, Mr Andrew King
Preston Royal Infirmary, Mr Aprajay Golash, Mr Nihal Gurusinghe
Western General Hospital, Edinburgh, Dr Rustam al-Shahi Salman
St. George's Hospital (Atkinson Morley's), London, Prof B A Bell
The Walton Centre, Liverpool, Mr Mohsen Javadpour, Mr Paul Eldridge
University Hospital of North Staffordshire, Mr Simon Shaw
Hull Royal Infirmary, Mr Shailendra Achawal
USA - Research Medical Center, Kansas, Dr Iftekar Ahmed
Hartford Hospital, Dr Inam Kureshi
Loyola University Hospital, Chicago, Dr Michael Schneck
Temple University Hospital, Philadelphia, Dr Michael Weaver
Central Illinois Neuroscience Foundation, Bloomington, Dr Keith Kattner
Georgia Neurosurgical Institute, Macon, Dr Arthur Grigorian
Albany Medical Centre, Dr John German
Mayo Clinic, Jacksonville, Dr Benjamin Eidelman
Penn State Hershey Medical Centre, Dr Kevin Cockroft
University of Louisville and Baptist Hospital East, Dr Jonathan E Hodes
University of Virginia Medical Center, Charlottesville, Dr Kenneth Liu
St. Joseph’s Candler Health System, Savannah, Dr Jay Howington
University of Illinois Medical Center at Chicago, Dr Sepidah Amin-Hanjani
Washington University School of Medicine, Dr Gregory Zipfel
early surgery group
Glasgow Coma Score
Glasgow Outcome Scale
Glasgow Outcome Scale - Extended (eight-point)
initial conservative treatment group
Surgical Trial in Intracerebral Haemorrhage
- STICH II:
Surgical Trial in Lobar Intracerebral Haemorrhage
The biggest acknowledgment goes to the patients who have given their informed consent to participate in this study and to the staff in our participating centres who provide a high level of support and make the research possible.
- Mendelow AD, Gregson BA, Mitchell PM, Murray GD, Rowan EN, Gholkar AR: STICH II investigators: Surgical trial in lobar intracerebral haemorrhage (STICH II) protocol. Trials [Electronic Resource]. 2011, 12: 124-Google Scholar
- Gregson BA, Broderick JP, Auer LM, Batjer H, Chen X-C, Juvela S, Morgenstern LB, Pantazis GC, Teernstra OPM, Wang W-Z, Zuccarello M, Mendelow AD: Individual patient data subgroup meta-analysis of surgery for spontaneous supratentorial intracerebral hemorrhage. Stroke. 2012, 43: 1496-1504. 10.1161/STROKEAHA.111.640284.View ArticlePubMedPubMed CentralGoogle Scholar
- Mendelow AD, Gregson BA, Fernandes HM, Murray GD, Teasdale GM, Hope DT, Karimi A, Shaw MD, Barer DH: STICH investigators: Early surgery versus initial conservative treatment in patients with spontaneous supratentorial intracerebral haematomas in the International Surgical Trial in Intracerebral Haemorrhage (STICH): a randomised trial. Lancet. 2005, 365: 387-397.View ArticlePubMedGoogle Scholar
- Mendelow A, Teasdale G, Barer D, FH F, Murray G, Gregson B: Outcome assignment in the International Surgical Trial in Intracerebral Haemorrhage. Acta Neurochirurgica (European Journal of Neurosurgery). 2003, 145: 679-681.View ArticleGoogle Scholar
- Murray G, Barer D, Choi S, Fernandes H, Gregson B, Lees K, Maas A, Marmarou A, Mendelow A, Steyerberg E, Taylor GS, Teasdale GM, Weir CJ: Design and analysis of phase III trials with ordered outcome scales: the concept of the sliding dichotomy. Journal of Neurotrauma. 2005, 22: 511-517. 10.1089/neu.2005.22.511.View ArticlePubMedGoogle Scholar
- Wilson JTL, Edwards P, Fiddes H, Stewart E, Teasdale GM: Reliability of postal questionnaires for the Glasgow Outcome Scale. Journal of Neurotrauma. 2002, 19: 999-1005. 10.1089/089771502760341910.View ArticlePubMedGoogle Scholar
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