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Background We conducted a randomized comparison of hydroxyurea with anagrelide in the treatment of essential thrombocythemia.
Methods A total of 809 patients with essential thrombocythemia who were at high risk for vascular events received low-dose aspirin plus either anagrelide or hydroxyurea. The composite primary end point was the actuarial risk of arterial thrombosis (myocardial infarction, unstable angina, cerebrovascular accident, transient ischemic attack, or peripheral arterial thrombosis), venous thrombosis (deep-vein thrombosis, splanchnic-vein thrombosis, or pulmonary embolism), serious hemorrhage, or death from thrombotic or hemorrhagic causes.
Results After a median follow-up of 39 months, patients in the anagrelide group were significantly more likely than those in the hydroxyurea group to have reached the primary end point (odds ratio, 1.57; 95 percent confidence interval, 1.04 to 2.37; P=0.03). As compared with hydroxyurea plus aspirin, anagrelide plus aspirin was associated with increased rates of arterial thrombosis (P=0.004), serious hemorrhage (P=0.008), and transformation to myelofibrosis (P=0.01) but with a decreased rate of venous thromboembolism (P=0.006). Patients receiving anagrelide were more likely to withdraw from their assigned treatment (P<0.001). Equivalent long-term control of the platelet count was achieved in both groups.
Conclusions Hydroxyurea plus low-dose aspirin is superior to anagrelide plus low-dose aspirin for patients with essential thrombocythemia at high risk for vascular events.
Hydroxyurea is widely used as first-line therapy for high-risk patients, often in combination with low-dose aspirin. A previous randomized study demonstrated that hydroxyurea controlled the platelet count and reduced the incidence of thrombotic events in patients with a high risk of thrombosis.8 Patients treated with hydroxyurea alone have a low incidence of leukemic transformation (3 to 4 percent),9,10 whereas those given more than one cytotoxic agent are at increased risk for acute myeloid leukemia. It is not clear whether this increased risk is an effect of the treatment or a consequence of aggressive disease.
Anagrelide was developed as an inhibitor of platelet aggregation but was later found to reduce the platelet count at doses lower than the amount required to inhibit platelet aggregation.11,12 The drug blocks megakaryocyte differentiation13,14 and proliferation15 and inhibits the action of cyclic AMP phosphodiesterase.16 Despite the lack of evidence of efficacy reported in a randomized trial, anagrelide is commonly used as first-line therapy for high-risk patients with essential thrombocythemia, even though it is substantially more expensive than hydroxyurea. Here we report the results of the United Kingdom Medical Research Council Primary Thrombocythemia 1 study, which compared hydroxyurea plus aspirin with anagrelide plus aspirin in patients with essential thrombocythemia at high risk for thrombosis.
Methods
Study Population
We conducted an open-label, randomized trial comparing hydroxyurea plus aspirin with anagrelide plus aspirin in patients with essential thrombocythemia at high risk for vascular events. Patients were eligible if they met diagnostic criteria for essential thrombocythemia and were at high risk for thrombotic or hemorrhagic events. Both patients with newly diagnosed disease and previously treated patients who were at least 18 years old were eligible.
We used the diagnostic criteria of the Polycythemia Vera Study Group for essential thrombocythemia.17 The Supplementary Appendix (available with the full text of this article at www.nejm.org) lists reasons for exclusion of patients from the study. Patients were classified as at high risk if they met one or more of the following criteria: an age of at least 60 years; current or previous platelet counts of 1 million per cubic millimeter or more; a history of ischemia, thrombosis, or embolism; hemorrhage caused by essential thrombocythemia; hypertension requiring therapy; and diabetes requiring the administration of a hypoglycemic agent.
In the United Kingdom, Ireland, and Australia, 815 patients were randomly assigned to receive one of the study drugs in 138 centers between August 20, 1997, and August 15, 2002. Six patients, three in each group, were misdiagnosed as having essential thrombocythemia (two patients with chronic myeloid leukemia, two with reactive thrombocytosis, one with idiopathic myelofibrosis, and one with polycythemia vera); these patients were excluded from the analysis. Of the remaining 809 patients, 404 were randomly assigned to receive hydroxyurea plus aspirin and 405 to receive anagrelide plus aspirin; patients in both groups were followed for a median of 39 months (range, 12 to 72). Only six patients were lost to follow-up, including four as a result of emigration. Complete follow-up information was available until the last visit of these six patients. The institutional research ethics committees in each center approved the study protocol, and written informed consent was obtained from all patients.
Patients who were assigned to receive hydroxyurea were started on 0.5 to 1 g daily; those assigned to receive anagrelide were started on 0.5 mg twice daily. Doses were subsequently adjusted to maintain the platelet count at less than 400,000 per cubic millimeter. Treatment was considered to have failed in patients whose platelet count was not less than 600,000 per cubic millimeter after having received the assigned therapy for at least three months; these patients left the study. All patients received aspirin at a daily dose of 75 mg (100 mg in Australia). If aspirin was contraindicated, alternative agents were used: dipyridamole in 13 patients and clopidogrel in 4 patients. The protocol recommended delaying the introduction of aspirin in patients with very high platelet counts.
Information that was recorded at each visit included thrombotic or hemorrhagic events or transformation to neoplasm, other adverse events, a full blood count, measurement of the spleen, and a list of all other medications the patient was receiving. Follow-up forms requesting details of principal end-point diagnoses were completed annually.
End Points
The composite primary end point was the time from randomization until the patient died from thrombosis or hemorrhage or had an arterial or a venous thrombotic event or a serious hemorrhage (see the Supplementary Appendix). Secondary end points were the time to the first arterial or venous thrombotic event or to the first serious hemorrhage; the time to death; the incidence of transformation to myelofibrosis, acute myeloid leukemia, myelodysplasia, or polycythemia vera; and control of the platelet count.
In the Supplementary Appendix, we list definitions of myocardial infarction, stroke, transient ischemic attack, deep-vein thrombosis, pulmonary embolism, serious hemorrhage, and transformation to acute myeloid leukemia, myelodysplasia, and polycythemia vera; also described is how transformation to myelofibrosis was determined.18,19,20,21,22,23,24 All primary and secondary end points that were reported before July 31, 2004, were validated by a committee of clinicians who were blinded to the patients' treatment assignments. Two clinicians evaluated each event independently, and the study chairman resolved any disagreements. A committee of three hematopathologists who were blinded to the treatment assignments reviewed the results of the bone marrow biopsies of all patients with myelofibrotic or other transformations. Two hematologists who were blinded to treatment assignments independently reviewed all bone marrow aspirates and peripheral-blood smears from patients with transformations, and the study chairman resolved any disagreements.
Statistical Analysis
To detect a doubling in the rate of the primary end point (from 2 percent to 4 percent per year)6,8 in either group over a median of four years of follow-up, with 80 percent power and a significance level of 0.05, we estimated that the trial would require that 560 patients be randomly assigned to a study group. Randomizations were undertaken and conveyed by telephone or fax to the Clinical Trial Service Unit in Oxford, United Kingdom. Minimization25 was used to ensure that equal numbers of patients were assigned to each group, both overall and within subgroups defined by previous treatment (no treatment vs. aspirin or cytoreductive therapy or both) and previous treatment assignment (for patients who were initially in groups at low and intermediate risk).
Annual interim analyses were assessed by the data monitoring committee of the Medical Research Council, which uses the Haybittle–Peto stopping guideline, a difference of at least 3 SE between the two groups.26 In 2002, this committee noted an excess of vascular events and deaths close to the boundary of 3 SE, together with an excess of myelofibrosis, other adverse events, and withdrawal from treatment. In 2003, the difference in vascular events and deaths exceeded the boundary of 3 SE, and the differences in myelofibrosis, other adverse events, and withdrawal from treatment were maintained. On September 1, 2003, the trial was closed and a letter sent to investigators recommending that they consider changing the treatment of participating patients from anagrelide to hydroxyurea. Because the Haybittle–Peto guideline is a conservative stopping rule, P values do not require adjustment for the interim analyses.27
Differences in baseline characteristics according to treatment assignment were assessed with the use of the chi-square test (two-by-two tables), the Mantel–Haenszel test for trend (with a grouped timing of trial entry), or the Mann–Whitney U test (for continuous data). Wilcoxon rank-sum tests were used to compare platelet counts between the two groups at three monthly time points for the first two years after randomization. Kaplan–Meier analysis and the log-rank test28 were used to compare time to event from randomization on an intention-to-treat basis, with data of surviving patients censored on August 31, 2003, or (for those lost to follow-up) on the date of the last follow-up. The observed number of events (O) minus the expected number of events (E) in the anagrelide group and its variance (V) were calculated from the log-rank survival analysis and used to calculate the odds ratio28 (as the exponent of [(O–E)÷V]). Tests for interaction were used to assess whether the treatment effect differed among subgroups of patients.29
In the Supplementary Appendix, we describe how the trial was conceived, conducted, and analyzed. Shire, the manufacturer of anagrelide, provided the drug at a reduced price but was otherwise not involved in the trial.
Results
Baseline Characteristics
There were no significant differences between the two groups with respect to laboratory and clinical features at diagnosis or trial entry (Table 1). The groups were well matched with respect to risk factors for thrombosis and hemorrhage and to hematologic transformation. Approximately one third of patients in each group had previously received hydroxyurea.
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Control of the platelet count was similar in the two groups by nine months after trial entry and subsequently (Figure 1). At three and six months after trial entry, platelet counts in the anagrelide group were significantly higher than those in the hydroxyurea group (P<0.001 for both time points). The difference remained significant when the analysis was restricted to patients with newly diagnosed disease at trial entry (data not shown) and therefore did not reflect a need for patients who had previously received a diagnosis of essential thrombocythemia to change from hydroxyurea to anagrelide after randomization to the anagrelide group. The median white-cell count in the hydroxyurea group was significantly and persistently lower than that in the anagrelide group (P<0.001), starting at three months after trial entry (data not shown).
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As compared with the hydroxyurea group, the anagrelide group had a significantly higher rate of the composite primary end point of arterial or venous thrombosis, serious hemorrhage, or death from vascular causes (odds ratio, 1.57; 95 percent confidence interval, 1.04 to 2.37; P=0.03) (Table 2). The estimated risk of the primary end point at five years was 16 percent in the anagrelide group (95 percent confidence interval, 12 to 21) and 11 percent in the hydroxyurea group (95 percent confidence interval, 7 to 14), with a median follow-up of 39 months (Figure 2). The rates of the primary end point were also compared in prespecified subgroups of patients (newly diagnosed vs. previously diagnosed disease; previous cytoreductive therapy vs. no previous cytoreductive therapy; and previous hydroxyurea therapy vs. no previous hydroxyurea therapy). There was no evidence of heterogeneity of treatment effect between these subgroups.
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Since patients who received anagrelide were more likely to withdraw from their assigned treatment than were patients who received hydroxyurea (Table 3), survival analyses were repeated with data that were censored on the date of the patients' withdrawal from treatment. The various rates of arterial or venous thrombosis, serious hemorrhage, and reaching the composite primary end point all remained statistically significant, with minimal changes in the P values (data not shown).
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Disease Transformation
As compared with the hydroxyurea group, the anagrelide group had a significantly increased rate of transformation to myelofibrosis (odds ratio, 2.92; 95 percent confidence interval, 1.24 to 6.86; P=0.01) (Table 2). The estimated actuarial risk of myelofibrosis five years after trial entry was 2 percent for the hydroxyurea group (95 percent confidence interval, 0 to 5) and 7 percent for the anagrelide group (95 percent confidence interval, 3 to 10) (Figure 3D). Of the 21 patients with myelofibrotic transformation, 3 had died by September 2003, all in the anagrelide group.
The increased rate of myelofibrosis in the anagrelide group remained evident after patients who had previously received busulfan were excluded from the analysis (P=0.04). None of the 21 patients had anemia, leukoerythroblastic findings on peripheral-blood smears, or systemic symptoms at trial entry, and only 1 (5 percent) had splenomegaly (as compared with 7 percent for the trial as a whole). Furthermore, the higher rate of myelofibrotic transformation was not an artifact of the precise definition that was used, since making the diagnostic criteria more stringent by requiring the inclusion of three clinical or laboratory features instead of two, or by the exclusion of any one of the five criteria from the set, did not affect the statistical significance.
Myelodysplasia or acute myeloid leukemia developed in 10 patients, 4 in the anagrelide group and 6 in the hydroxyurea group (Table 2). Median survival was 14 months from transformation, and seven patients had died by September 2003. Polycythemia vera developed in two patients (one in each group), at 3 and 49 months after trial entry.
Safety and Side Effects
The number of patients who withdrew from the assigned treatment before closure of the trial was higher in the anagrelide group than in the hydroxyurea group (148 vs. 79, P<0.001) (Table 3). Significantly more patients withdrew from the anagrelide group because of side effects (88 vs. 43, P<0.001) or because either an end point (particularly myocardial infarction or hematologic transformation) or a serious adverse event had developed (most commonly, cardiac failure, serious arrhythmia, or pancytopenia). The lower rate of withdrawal from treatment with hydroxyurea was still evident even when analysis was restricted to patients who had not previously received hydroxyurea (P<0.001).
The rates of nonthrombotic cardiovascular events (particularly palpitations), gastrointestinal events (especially diarrhea and abdominal pain), noncardiac edema, headache, and constitutional symptoms were all significantly higher in the anagrelide group (Table 3). The rate of dermatologic side effects, including mouth ulcers, was significantly increased in the hydroxyurea group.
Discussion
This study of more than 800 patients with essential thrombocythemia who were at high risk for thrombosis shows that, as compared with hydroxyurea plus aspirin, anagrelide plus aspirin was associated with higher rates of arterial thrombosis, serious hemorrhage, transformation to myelofibrosis, and treatment withdrawal but a lower rate of venous thromboembolism. The participation of many secondary and tertiary hematology centers and the involvement of three countries suggest that these conclusions can be generalized.
The rates of major arterial and venous thrombosis in the hydroxyurea group in this trial were similar to those in the hydroxyurea group in the study of Cortelazzo and colleagues8 (actuarial rate of first thrombosis, 4 percent at two years in both trials), which suggests that the study populations in the two trials were broadly similar. However, the rate of major arterial and venous thrombosis in the anagrelide group in our trial was less than that observed in the control group (which did not receive hydroxyurea) in the Italian study (actuarial rate of first thrombosis, 8 percent vs. 26 percent at two years, respectively). Since more than 80 percent of the thrombotic events in the Italian trial were arterial, these comparisons suggest that anagrelide partially protects against arterial thrombosis. It is interesting to note that both trials reported a marked effect of hydroxyurea on rates of transient ischemic attack, which suggests a particular role for hydroxyurea in the prevention of this complication.
In contrast to the rate of arterial thrombosis, the rate of venous thrombosis was significantly lower in the anagrelide group. Since the incidence of venous thrombosis in untreated patients with high-risk essential thrombocythemia is unknown, it is unclear whether this rate is increased by hydroxyurea or decreased by anagrelide. The optimal treatment of a patient with prior venous thrombosis will depend not only on individual circumstances but also on the fact that arterial thrombosis is more than three times more common than venous thrombosis in essential thrombocythemia.
The equivalent long-term control of the platelet count in both groups implies that, in addition to lowering the platelet count, either hydroxyurea or anagrelide may modulate thrombosis by other mechanisms. The lower white-cell count in patients receiving hydroxyurea may be relevant, since white cells contribute to the procoagulant response at sites of vascular injury.30 Moreover, neutrophil activation occurs in essential thrombocythemia and correlates with activation of both endothelial cells and the coagulation cascade.31 Hydroxyurea also has direct effects on endothelial function32 and acts as a nitric oxide donor.33
The increased risk of serious hemorrhage in the anagrelide plus aspirin group may reflect interference of anagrelide with platelet function in a way that synergizes with low-dose aspirin. Anagrelide blocks platelet phosphodiesterase activity16 and at high doses (0.5 to 10.0 mg per kilogram of body weight) inhibits thrombus formation in animal models.34 Although the results of most assays of platelet function are normal in patients with essential thrombocythemia who receive anagrelide, some subtle effects on platelet function have been reported.35,36 The results presented here suggest that if anagrelide is used, the decision whether to use concurrent aspirin therapy should depend on the relative risk of arterial thrombosis and hemorrhage in each patient.
The incidence of transformation to myelofibrosis was higher in the anagrelide group than in the hydroxyurea group. The reason for this difference is unknown. Hydroxyurea reduces reticulin fibrosis in a variety of myeloproliferative disorders, including essential thrombocythemia.37,38 By contrast, the many immature forms that arise when anagrelide blocks differentiation of megakaryocytes may produce relatively high levels of profibrotic cytokines.
In summary, the results of this trial suggest that hydroxyurea plus aspirin should remain first-line therapy for patients with essential thrombocythemia at high risk for vascular events.
Supported by the United Kingdom Medical Research Council and by a grant from the Medical Research Council (to Ms. Buck) and a grant from the Leukaemia Research Fund (to Dr. Campbell).
We are indebted to Professor Tom Pearson for his central role in the design and early stages of this trial and for his subsequent unstinting support, and to all the staff members who provided randomization service at the Clinical Trial Service Unit, Radcliffe Infirmary, Oxford, United Kingdom.
Source Information
From the Department of Haematology, University of Cambridge, and Addenbrooke's National Health Service Trust, Cambridge (P.J.C., C.L.E., A.R.G.); the Departments of Haematology and Histopathology, St. Thomas Hospital, London (C.N.H., J.D.W.); the Clinical Trial Service Unit, Radcliffe Infirmary, Oxford (G.B.); Birmingham Clinical Trials Unit, University of Birmingham, Birmingham (K.W.); the Department of Haematology, City Hospital National Health Service Trust, Birmingham (D.B.); the Department of Histopathology, Royal Victoria Infirmary, Newcastle-upon-Tyne (B.S.W.); the Department of Haematology, University of Sheffield, Sheffield (J.T.R.); the Department of Haematology, Staffordshire General Hospital, Stafford (P.R.); and the Department of Haematology, Southport and Formby District General Hospital, Southport (B.E.W.) — all in the United Kingdom; and the Department of Haematology, Royal Melbourne Hospital, Melbourne, Australia (A.P.G.).
Address reprint requests to Dr. Green at the Department of Haematology, Cambridge Institute of Medical Research, Hills Rd., Cambridge CB2 2XY, United Kingdom, or at arg1000{at}cam.ac.uk.
References
Trial coordinators: A.R. Green, C.N. Harrison, T.C. Pearson; Histopathology Committee: D. Bareford, J.D. van der Walt, B.S. Wilkins; Clinical Events Committee: P.J. Campbell, A.R. Green, C.N. Harrison; United Kingdom Myeloproliferative Disorders Study Group: D. Bareford, P.J. Campbell, E. Conneally, C. Crawley, N.C.P. Cross, A.R. Green, G. Hall, C.N. Harrison, B. Hunt, G. Lucas, C. Ludlam, M.F. McMullin, D. Oscier, D. Radia, J.T. Reilly, G. Robinson, J.D. van der Walt, and B.S. Wilkins. The following investigators and clinical centers randomized high-risk patients (number of patients enrolled in brackets): United Kingdom — Aberdeen Royal Infirmary, Aberdeen: D.J. Culligan (2), J. Tighe (1), H.G. Watson (7); Addenbrooke's National Health Service Trust, Cambridge: A.R. Green (24), A.J. Warren (3); Alexandra Hospital, Redditch: M.O. Awaad (2), D. Obeid (3); Altnagelvin Area Hospital, Londonderry: R.J.G. Cuthbert (8); Antrim Area Hospital, Antrim: A. Kyle (1); Barnsley District General Hospital, Barnsley: D. Chan-Lam (2); Basildon Hospital, Basildon: P. Cervi (6); Bassetlaw Hospital, Worksop: B. Paul (10); Belfast City Hospital, Belfast: R.J.G. Cuthbert (2), M.F. McMullin (8), T.C.M. Morris (1); Birmingham Heartlands Hospital, Birmingham: R.J. Johnson (1), C. Fegan (7), D.W. Milligan (11); Bishop Auckland General Hospital, Bishop Auckland: M.J. Galloway (4), P.J. Williamson (1); Bradford Royal Infirmary, Bradford: L.J. Newton (1), A.T. Williams (1); Central Middlesex Hospital, London: Z. Abboudi (1), K. Ryan (3); Cheltenham General Hospital, Cheltenham: R. Lush (1), E. Blundell (1), R.G. Dalton (3); City Hospital National Health Service Trust, Birmingham: D. Bareford (26), J.G. Wright (6); Colchester General Hospital, Colchester: M. Wood (7); Conquest Hospital, St. Leonard's on Sea: J. Beard (2); Countess of Chester Hospital, Chester: J.V. Clough (2), E. Rhodes (4); Craigavon Area Hospital, Armagh: H.K. Boyd (2), C. Humphrey (1); Dartford and Gravesham National Health Service Trust, Dartford: C.C. Ozanne (1); Derbyshire Royal Infirmary, Derby: D.C. Mitchell (6), S. Mayne (2); Dewsbury and District Hospital, Dewsbury: M.R. Chapple (1); Doncaster Royal Infirmary, Doncaster: B. Paul (1); Dumfries and Galloway Royal Infirmary, Dumfries: R.K.B. Dang (1), A. Stark (1), F. Toolis (1); Epsom General Hospital, Epsom: L. Jones (1); Freeman Hospital, Newcastle upon Tyne: J.P. Wallis (1); George Eliot Hospital, Nuneaton: A.H.M. Abdul-Cader (1), M. Narayanan (1); Glasgow Royal Infirmary, Glasgow: G. McQuaker (1); Gloucestershire Royal Hospital, Gloucester: R. Lush (1), J. Ropner (2); Good Hope Hospital National Health Service Trust, Sutton Coldfield: M.S. Hamilton (4), S.M. Jobanputra (3), J. Tucker (6); Great Western Hospital, Swindon: N.E. Blesing (3), A.G. Gray (2), E.S. Green (6); Harrogate District Hospital, Harrogate: M.W. McEvoy (2); Hemel Hempstead General Hospital, Hemel Hempstead: E.J. Gaminara (2), J.F.M. Harrison (4); Hereford County Hospital, Hereford: S.J.B. Willoughby (7); Hillingdon Hospital, Uxbridge: R. Jan-Mohamed (6), R. Kaczmarski (1); Hinchingbrooke Hospital, Huntingdon: C.E. Hoggarth (1), K. Rege (2); Huddersfield Royal Infirmary, Huddersfield: C. Carter (1); Hull Royal Infirmary, Hull: K. Patil (4), R.D. Patmore (1), M.L. Shields (9), S. Ali (1); Inverclyde Royal Hospital, Greenock: D.L. Ellis (2); Ipswich Hospital, Ipswich: J.A. Ademokun (2), I.H.M. Chalmers (2); James Cook University Hospital, Middlesbrough: J.G. Hudson (1), A.C. Wood (1); James Paget Hospital, Great Yarmouth: M.T. Jeha (3), S. Sadullah (1); Kent and Canterbury Hospital, Canterbury: M. Leahy (4), C.F.E. Pocock (3); Kidderminster Hospital, Kidderminster: M.L. Lewis (3); King Edward VII Hospital, West Sussex: J.A. Shirley (1); King's College Hospital, London: R. Arya (3); King's Mill Hospital, Sutton-in-Ashfield: M. Auger (2); Leeds General Infirmary, Leeds: G.M. Smith (1); Leicester Royal Infirmary, Leicester: R.M. Hutchinson (3), J. Pasi (1), C.S. Chapman (1), A.E. Hunter (5), V.E. Mitchell (2), J.A. Snowden (1), J.K. Wood (1); Lincoln County Hospital, Lincoln: M.A. Adelman (1); Lister Hospital, Stevenage: C. Tew (2); Manor Hospital, Walsall: A. Jacob (1); Mayday Hospital, Thornton Heath: C.M. Pollard (2); Milton Keynes General National Health Service Trust, Milton Keynes: E.J. Miller (1); Monklands District General, Airdrie: J.A. Murphy (2), R. Soutar (1), W. Watson (1); Nevill Hall Hospital, Gwent: H.W. Habboush (4), G.T.M. Robinson (5); Newark Hospital, Newark: S.M. Donohue (1); Norfolk and Norwich University Hospital, Norwich: A.M. Deane (6), G.E. Turner (4), J.Z. Wimperis (7); North Devon District Hospital, Barnstaple: B. Attock (1); North Hampshire Hospital, Basingstoke: D.L. Aston (1), A.E. Milne (4), T.J.C. Nokes (1); North Middlesex Hospital, Edmonton: T. Kumaran (1); North Staffordshire Hospital Centre, Hartshill: R.C. Chasty (5); Northwick Park Hospital, Harrow: S. Allard (2), C.D.L. Reid (7); Oldchurch Hospital, Romford: A. Brownell (5), D. Lewis (3); Oxford Radcliffe Hospitals, Oxford: T.J. Littlewood (7); Pembury Hospital, Tunbridge Wells: D.S. Gillett (5); Pontefract General Infirmary, Pontefract: D. Wright (5); Poole Hospital National Health Service Trust, Poole: A.J. Bell (1), F. Jack (3); Princess Alexandra Hospital, Harlow: V. Oxley (2); Princess Royal Hospital, Haywards Heath: P.R. Hill (6); Princess Royal University Hospital, Orpington: C.F.M. De Lord (5), A.K. Lakhani (1), B. Vadher (1); Queen Elizabeth Hospital, Birmingham: J.A. Murray (7), P. Mahendra (3); Queen Elizabeth Hospital, King's Lynn: J. Keidan (3), P. Coates (1); Queen Elizabeth Hospital, Tyne and Wear: G.P. Summerfield (1); Queen Elizabeth II Hospital, Welwyn Garden City: J.M. Voke (6); Queen Margaret Hospital, Dunfermline: A. Evan-Wong (5); Raigmore Hospital, Inverness: P. Forsyth (1), W. Murray (1); Rotherham District General, Rotherham: H.F. Barker (10), B. Paul (3), P.C. Taylor (6); Royal Alexandra Hospital, Renfrewshire: P. McKay (6); Royal Berkshire Hospital, Reading: F.B. BritoBabapulle (1), H. Grech (9); Royal Bournemouth Hospital, Bournemouth: T.J. Hamblin (1), D.G. Oscier (7); Royal Chesterfield Hospital, Chesterfield: R. Collin (6), R. Stewart (2), M. Wodzinski (1); Royal Cornwall Hospital, Truro: M.D. Creagh (5), A.R. Kruger (8), R. Noble (2); Royal Devon and Exeter Hospital, Exeter: R. Lee (1), M.A. Pocock (1), C.E. Rudin (1); Royal Free Hospital, London: M.N. Potter (1), A.B. Mehta (1); Royal Gwent Hospital, Gwent: H.A. Jackson (2), E.H. Moffat (1); Royal Hallamshire Hospital, Sheffield: J.T. Reilly (12), D.A. Winfield (1); Royal Infirmary of Edinburgh, Edinburgh: E.H. Horn (1), P.R.E. Johnson (6), C.A. Ludlam (10); Royal Lancaster Infirmary, Lancaster: D.W. Gorst (7); Royal Liverpool University Hospital, Liverpool: R.E. Clark (4), A.R. Pettitt (1), P. Chu (1); Royal London Hospital, London: J.D. Cavenagh (1); Royal Surrey County Hospital, Guildford: I.D.C. Douglas (1), G. Robbins (2); Royal United Hospital National Health Service Trust, Bath: C.J.C. Knechtli (1); Russells Hall Hospital, West Midlands: P. Harrison (5), J. Neilson (1); Salford Royal Hospitals National Health Service Trust, Salford: J.B. Houghton (2); Salisbury District Hospital, Salisbury: J.O. Cullis (6), H.F. Parry (2); Sandwell General Hospital, West Bromwich: S.I. Handa (3), Y. Hasan (1), P.J. Stableforth (4); Scunthorpe General Hospital, Scunthorpe: R.A. Ezekwesili (2), S. Jalihal (6); Singleton Hospital, Swansea: S. Al-Ismail (9), M.S. Lewis (2); South Tyneside Hospital, Tyne and Wear: A.M. Hendrick (1); Southampton University Hospital, Southampton: A. Duncombe (5); Southern General Hospital, Glasgow: L.M. Manson (2), A.E. Morrison (5); Southport District General, Southport: B.E. Woodcock (13); St. Helier Hospital, Carshalton: J. Behrens (3), J. Mercieca (1); St. Johns Hospital, Livingston: M.K. Cook (5); St. Mary's Hospital, London: B.J. Bain (4), A.A. Shlebak (3); St. Richard's Hospital, Chichester: P.C. Bevan (1), S.L. Janes (3), P. Stross (2); St. Thomas' Hospital, London: M. Messinezy (2), T.C. Pearson (1); Staffordshire General Hospital, Stafford: T.A.J. Phaure (1), P. Revell (15); Stepping Hill Hospital, Stockport: S. Jowitt (3), H.M Leggat (1); Stoke Mandeville Hospital, Aylesbury: S.M. Sheerin (1), A. Watson (9); Taunton and Somerset National Health Service Trust, Taunton: S. Bolam (1), S.V. Davies (2); Torbay Hospital, Torquay: F. Booth (2), N. Rymes (1), S.R. Smith (11), D.L. Turner (1); Ulster Hospital, Belfast: M. El-Agnaf (4); University Hospital Aintree, Liverpool: A. Olujohungbe (2); University Hospital Lewisham, London: N. Mir (3), M.L. Tillyer (6); University Hospital of Wales, Cardiff: G.T.M. Robinson (2), A.K. Burnett (5), C. Poynton (4); Vale of Leven District General Hospital, Dunbartonshire: P. Clarke (1); Victoria Hospital, Kirkcaldy: C.J. McCallum (9), S.Y. Rogers (1); Wansbeck General Hospital, Ashington: I. Neilly (1); West Middlesex Hospital, London: R.G. Hughes (4), M. Sekhar (5); Western General Hospital, Edinburgh: P. Ganly (1), P.R.E. Johnson (3), M.J. Mackie (6), A.C. Parker (1), P.H. Roddie (3); Wexham Park Hospital, Slough: N. Bienz (1), P.H. Mackie (1); Whipps Cross Hospital, London: C. DeSilva (1); Whittington Hospital, London: N.E. Parker (3); Withybush General Hospital, Haverfordwest: A.K.N. Saleem (3); Worthing Hospital, Worthing: C.L. Rist (1), A.W.W. Roques (6); Wrexham Maelor Hospital, Wrexham: J. Duguid (1); Wycombe General Hospital, High Wycombe: R. Aitchison (2), S. Kelly (1), J.K. Pattinson (7); Ysbyty Gwynedd, Bangor: M. Gilleece (1), H.E.T. Korn (1), D.H. Parry (3), J.R.C. Seale (1); Australia — Fremantle Hospital, Fremantle: J.P. Cooney (1), F. Cordingley (1), M.F. Leahy (1); Peter Maccallum Cancer Institute, Victoria: H. Januszewicz (2), M. Prince (1); Royal Hobart Hospital, Hobart: R. Young (1); Royal Melbourne Hospital, Victoria: A. Grigg (13); Ireland — University College Hospital, Galway: M. Murray (1).
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