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We conducted an international study of idiopathic pulmonary fibrosis (IPF) diagnosis among a large group of physicians and compared their diagnostic performance to a panel of IPF experts.
A total of 1141 respiratory physicians and 34 IPF experts participated. Participants evaluated 60 cases of interstitial lung disease (ILD) without interdisciplinary consultation. Diagnostic agreement was measured using the weighted kappa coefficient (κw). Prognostic discrimination between IPF and other ILDs was used to validate diagnostic accuracy for first-choice diagnoses of IPF and were compared using the C-index.
A total of 404 physicians completed the study. Agreement for IPF diagnosis was higher among expert physicians (κw=0.65, IQR 0.53–0.72, p<0.0001) than academic physicians (κw=0.56, IQR 0.45–0.65, p<0.0001) or physicians with access to multidisciplinary team (MDT) meetings (κw=0.54, IQR 0.45–0.64, p<0.0001). The prognostic accuracy of academic physicians with >20 years of experience (C-index=0.72, IQR 0.0–0.73, p=0.229) and non-university hospital physicians with more than 20 years of experience, attending weekly MDT meetings (C-index=0.72, IQR 0.70–0.72, p=0.052), did not differ significantly (p=0.229 and p=0.052 respectively) from the expert panel (C-index=0.74 IQR 0.72–0.75).
Experienced respiratory physicians at university-based institutions diagnose IPF with similar prognostic accuracy to IPF experts. Regular MDT meeting attendance improves the prognostic accuracy of experienced non-university practitioners to levels achieved by IPF experts.
Academic status, access to MDT meetings and clinician experience predict accuracy of a clinical diagnosis of IPF http://ow.ly/k43W30cTMg1
Idiopathic pulmonary fibrosis (IPF) is characterised by progressive loss of lung function and a particularly poor prognosis . Although it is often regarded as a rare disorder, in 2012 1% of all deaths in the UK occurred because of pulmonary fibrosis  and the incidence of IPF is expected to continue to rise [3–8]. Accurate IPF diagnosis has increased in importance with the advent of antifibrotic therapies and ongoing enrolment in IPF treatment trials [9, 10].
Although the ATS/ERS/JRS/ALAT guideline diagnostic recommendations emphasise the importance of a multidisciplinary approach when diagnosing IPF [11–13], less experienced non-academic clinicians outside regional centres may not have access to multidisciplinary team (MDT) meetings . Therefore, the diagnostic accuracy of clinicians acting in isolation is of practical importance. In the absence of a reference standard, one approach to evaluating the diagnostic skills of clinicians is to examine separations in mortality between patients diagnosed with IPF and those diagnosed with other ILDs, a method used in a recent study of multidisciplinary diagnosis . The most accurate discrimination between IPF and non-IPF diagnoses should, in principle, provide the greatest separation in outcomes.
The aim of this study was to evaluate and compare IPF diagnoses made by non-academic clinicians, university-affiliated clinicians and an international panel of IPF experts, using three surrogates of diagnostic accuracy: diagnostic confidence, diagnostic agreement and prognostic accuracy (which was examined in non-expert subgroups against years of experience and access to an MDT meeting).
The study protocol was approved by the NHS Health Research Authority, and for this retrospective examination of clinically indicated data, the need for patient consent was waived. We selected consecutive patients presenting to the interstitial lung disease (ILD) unit of the Royal Brompton and Harefield NHS Foundation Trust (London, UK) between January 5, 2010, and October 25, 2010 (supplementary figure A1). This approach allowed an analysis of 5-year survival and also meant that patients included in the study were selected from a pre-antifibrotic therapy era. Therefore, outcome distinctions between patients with IPF and those without this disease were not confounded by antifibrotic therapy. Since referral rates of patients with suspected IPF to the host institution in 2010 differed (25% of all referrals) from 2015 (36% of all referrals), we enriched the cohort with consecutive patients referred to the host institution between January 5, 2010, and October 25, 2010, and who were diagnosed with IPF by the host institution, to match 2015 IPF referral rates. Exclusion criteria were as follows.
1) An established diagnosis of connective tissue disease prior to presentation to the host institution. In these patients, the diagnosis of connective tissue disease-related ILD is usually straightforward and might spuriously increase overall diagnostic agreement .
2) Non-availability of imaging or lung function tests at presentation.
3) Diffusing capacity of the lung for carbon monoxide (DLCO) <30% predicted, excluded because: a) clinicians might assume that the presence of end-stage fibrosis indicates IPF thus impacting diagnostic agreement and accuracy for an IPF diagnosis; b) although patients with end-stage fibrotic lung disease may occasionally be referred to the host institution, this may not reflect referral patterns to less specialised centres; and c) treatment may be less effective in patients with end-stage fibrosis reducing the importance of diagnostic precision.
Between January 1, 2015, and July 1, 2016, we performed an Internet search, country by country, for practising respiratory physicians. Physician experience, nationality, academic status (working at a university hospital or not a university hospital) or subspecialist interests within respiratory medicine did not influence inclusion eligibility. This search included the European Respiratory Society Diffuse Parenchymal Lung Disease Assembly and the American Thoracic Society Clinical Problems Assembly. During July 2016 an invitation to participate in the study was extended to all of the physicians identified. In addition to this group, an expert panel was created, comprising respiratory physicians with specialist expertise in the diagnosis and management of ILD working in specialist ILD centres and with a track record of publications in this field. For the purposes of this study, physicians working at university-affiliated institutions are referred to as university physicians or academic physicians, and physicians not working at university-affiliated institutions are referred to as non-university physicians or non-academic physicians.
Evaluation of cases took place between July 1, 2016, and January 1, 2017, on a custom built web-based application. First, physicians were required to answer a preliminary survey regarding their usual clinical practice (supplementary table A1). Then for each case they were presented with the patient's history, findings on physical examination and standardised baseline clinical information, extracted from the patient electronic records (supplementary table A2). Physicians were provided the presentation high-resolution computed tomography scan (HRCT). The original HRCT report was not provided. We did not inform physicians if the host institution had performed surgical lung biopsy. Since biopsy decisions depend on a physician's individual clinical judgement, there would be no way of knowing which patients would eventually have undergone a lung biopsy. Also, if we had provided biopsy information, the clinical skill of the physician would be influenced by the expertise of the host institution.
The scoring protocol has been described previously . For each case, physicians were required to select up to five differential diagnoses and provide a diagnostic likelihood (censored at 5% and summing to 100% in each case) from a drop-down menu of diffuse lung diseases (supplementary table A3) based upon their diagnostic confidence. The drop-down menu included a category labelled “other”, to be selected when the desired diagnosis was not listed. In this situation, physicians were required to provide their diagnosis in a free-text box. The only stipulation to scoring the cases was that each case was evaluated in isolation without interspecialty consultation.
Statistical analyses were performed using STATA (version 14, StataCorp, College Station, TX, USA). Data are given as means with standard deviations (sd), medians with interquartile range (IQR) or as the number of patients and percentage where appropriate. Group comparisons were made using the t-test, Wilcoxon rank sum, chi-squared statistics and Fisher's exact test where appropriate.
Cohen's kappa coefficient (κ) was used to evaluate interobserver agreement for diagnosis and the weighted kappa coefficient (κw) was used to evaluate interobserver agreement for an estimation of the probability of each diagnosis. To do this, the percentage diagnostic likelihood given for each diagnosis was converted to a 5-point scale (0–4), representing clinically useful probabilities: 0=condition not included in the differential diagnosis, 1=low probability (5–25%), 2=intermediate probability (30–65%), 3=high probability (70–95%) and 4=pathognomonic (100%). This approach has been used in previous investigations of interobserver agreement for the diagnosis of diffuse lung diseases (supplementary material) [15–17]. Weighted kappa values were calculated between paired observers and expressed as median values with interquartile ranges for all unique combinations of pairs. Weighting the kappa coefficient allowed the degree of disagreement to be quantified by assigning greater emphasis to large differences between scores. Additionally, for each patient the first-choice diagnosis was considered high confidence if the diagnostic likelihood assigned was ≥70%. This distinction is based on the diagnostic likelihood categories used to assess the clinical probability of pulmonary embolism in the PIOPED study  and has been used in another study of diagnostic agreement .
We used outcome distinctions between IPF and other diffuse lung diseases to validate diagnostic accuracy for IPF by converting each physician's first-choice diagnosis into a binary IPF diagnosis category (IPF or not IPF). Cox proportional hazards modelling was then used to determine a hazard ratio (HR) for each physician, adjusted for disease severity by including per cent predicted DLCO in the regression model. Time to death was the outcome for survival analyses and the survival period for each patient was calculated from the date of referral to the host institution to January 1, 2015. We tested the assumptions of proportional hazards by visual inspection of the log–log plot of survival, comparison of the Kaplan–Meier observed survival curves with the Cox predicted curves for the same variable and graphical and formal analysis of Schoenfeld residuals (analysis not shown). Results are reported as HR, 95% CI and p values. The prognostic accuracy of individual physician diagnoses was quantified using Harrell's C-index, which when used in this context, is a measure of prognostic discrimination (supplementary material) .
Multivariate linear regression models were used to identify independent predictors of prognostic accuracy within physician subgroups (expert, university, non-university and those with and without access to MDT meetings) taking the C-index as the dependent variable and using a backward elimination procedure, retaining variables with p<0·05. The assumptions of linear regression were tested and confirmed by inspection of residual-versus-predictor plots and heteroskedasticity was tested for graphically (by inspection of residuals plotted against fitted values) and non-graphically (using the Cook–Weisberg test for heteroskedasticity). The diagnostic performance of various subgroups of physicians based on these predictors was then compared to the expert panel group
The total cohort of cases was made up of 60 patients, including 22 (36.7%) with an MDT meeting diagnosis of IPF. Five patients required surgical lung biopsy. Three of these were diagnosed as IPF, one as pulmonary alveolar proteinosis and one as obliterative bronchiolitis. Vital status was known for all patients at the end of the study period. There were 26 out of 60 (43.4%) deaths at the end of the study period. Mean follow-up periods for IPF and non-IPF cases were 1246.0 days and 1646.0 days respectively. For more details of patient exclusions, diagnoses and mortality, see the supplementary material and supplementary table A4.
A total of 1141 respiratory physicians from 102 countries were invited to participate in the study. Between July 7, 2016, and January 1, 2017, 750 physicians representing 76 countries enrolled and completed the preliminary survey. Of these, 404 physicians, representing 57 countries, which included a panel of 34 invited experts, completed the evaluation of all 60 cases. Physicians who completed the study were more likely to be fellowship trained, work at university hospitals, have access to MDT meetings and diagnose more cases of IPF per month (tables 1 and and2).2). A summary of physician demographics based on country is shown in supplementary table A5.
A total of 24240 case evaluations were performed (404 physicians×60 cases). IPF made up 6308 (26.0%) of all first-choice diagnoses. Of the IPF diagnoses, 72.3% were made with high confidence (diagnostic likelihood ≥70%). Expert panel members and academic physicians made high confidence diagnoses of IPF more frequently than non-academic physicians (p=0.002 and p=0.001, table 3) and more frequently diagnosed IPF overall (p=0.005 and p=0.008, table 3). Attendance at MDT meetings was not associated with a higher frequency of IPF diagnoses or a higher frequency of highly confident IPF diagnoses (p=0.718, p=0.925, table 3).
Overall interobserver agreement for the first-choice diagnosis of IPF was moderate for the entire cohort of physicians (n=404, κ=0.42). Unweighted Kappa values for interobserver agreement for a diagnosis of IPF for various physician subgroups are shown in table 4. The greatest diagnostic agreement for the first-choice diagnosis of IPF was between the expert panel members (n=34, κ=0.53). Physicians with no access to MDT meetings had the lowest level of diagnostic agreement for the first-choice diagnosis of IPF (n=76, κ=0.35) (table 4). Agreement on the likelihood of an IPF diagnosis (ranging from <5% to >95%) was highest among expert physicians, academic physicians and physicians with access to MDT meetings (table 5). Interobserver agreement for the likelihood of an IPF diagnosis between physicians based on country is shown in supplementary table A6.
Diagnoses of IPF were prognostically significant for 318 of 404 respiratory physicians (68.6%, median HR 2.81, IQR 2.21–3.61; median C-index=0.72, IQR 0.70–0.74). The range of C-indices across the entire cohort of physicians was 0.69–0.81. Hazards ratios, p values and C-indices for all participating physicians based on country are shown in supplementary table A7. Expert physicians, compared to other physicians, were more likely to make prognostically significant IPF diagnoses (29/34, 85.2%, versus 246/370, 66.4%; p=0.02) and with greater prognostic discrimination (as judged by C-indices), p=0.0002 (supplementary table A8). Academic physicians demonstrated greater prognostic discrimination for a diagnosis of IPF than non-university based hospital physicians, p=0.0006 (supplementary table A9). Physicians who attend MDT meetings demonstrated greater prognostic discrimination for a diagnosis of IPF than physicians not attending MDT meetings, p=0.004, supplementary table A10).
Multivariate linear regression analysis was performed taking the C-index as the dependent variable and 1) academic status, 2) years of experience (stratified by thresholds ranging from 5–35 years in 5-year increments), 3) MDT meeting attendance and 4) the number of IPF cases diagnosed per month as the independent variables. Academic status, >20 years of experience and attendance at MDT meetings independently predicted the prognostic accuracy of IPF diagnosis (supplementary table A11). Subsequent analyses of particular interest are summarised in table 6. Specifically, 1) university hospital physicians with >20 years of experience achieved equivalent prognostic discrimination to the expert panel for a diagnosis of IPF (or not IPF group), regardless of attendance at weekly MDT meetings (table 6, supplementary figure A2); 2) non-university hospital physician prognostic discrimination did not reach that of the expert panel, regardless of availability of MDT meetings or the threshold of 20 years of experience (table 6, supplementary figure A2); 3) however, non-university hospital physicians with >20 years of experience, attending weekly MDT meetings, demonstrated near expert level prognostic accuracy (C-index 0.72, IQR 0.70–0.72; p=0.052).
Our results show that academic status, attendance at MDT meetings and experience level of physicians are independently associated with greater prognostic discrimination between diagnoses of IPF and other ILDs. In particular, using mortality to validate accuracy of IPF diagnosis, we have shown that accuracy of IPF diagnosis made by university hospital-based practitioners with greater than 20 years of experience is equivalent to that of international IPF experts.
A recent study reported near parity in diagnostic agreement and accuracy for IPF between expert physicians and their respective MDT meetings . The purpose of this study was to investigate whether these findings could also be applied to physicians of varying levels of experience when acting in isolation without the benefit of MDT meeting evaluation. A central feature of our study was that we validated IPF diagnosis against mortality, an approach used in a previous study of diagnostic agreement and accuracy in IPF . In diffuse lung disease, multidisciplinary discussion is the recommended approach to diagnosis, which involves integrating all available clinical, radiologic and if available, pathologic data. For this reason, there is no reference standard against which the veracity of MDT diagnosis can be tested. However, as a poor outcome is a cardinal feature of IPF, accurate diagnosis should, in principle, provide the greatest prognostic discrimination between IPF and other ILDs.
The use of the C-index to examine prognostic accuracy between physician subgroups warrants further discussion. The range of achievable C indices for the 404 clinicians was narrow (from 0.69 to 0.81, therefore representing a 13-point scale) and is likely to reflect the fact that some non-IPF patients do badly and so misclassification of a non-IPF patient as an IPF patient might not significantly impact the C-index. Given this outcome overlap between the two disease groups, apparently small cohort shifts are likely to be more meaningful than they appear. Furthermore, as an example, the difference between a C-index of 0.70 and 0.72 is 15.4%, representing an upward shift in prognostic accuracy of 15.4% when comparing a population of experienced academic clinicians with MDT access to a population of less experienced (<20 years) non-academic clinicians without MDT access. This is in fact a large difference when, for example, it is compared with cohort shifts in serial forced vital capacity (FVC) in IPF antifibrotic trials, put up against the range of baseline FVC values.
Although several studies have reported that MDT diagnosis is associated with higher levels of diagnostic confidence and superior interobserver agreement when compared with the individual components of the MDT in isolation [15, 20, 21], the effect that MDT meetings have on individuals has not been examined. One of the assumed benefits of a multidisciplinary approach to IPF diagnosis is that those participating have their diagnostic thinking subjected to peer scrutiny. The regular interspecialty discussion that MDT meetings promote is likely to broaden a physician's experience and establish an ethos of debate and critical evaluation. Conceivably, physicians who are accustomed to this process gain skill in related disciplines such as HRCT interpretation, which they can use outside the multidisciplinary setting. For some physicians, increasing patient numbers and possibly referrals from other centres will mean that full MDT meeting characterisation is possible only for selected cases. Therefore, just as in this study, it is likely that a substantial number of IPF patients will receive a diagnosis made by their respiratory physician acting in isolation. In a recent national survey conducted in France, IPF diagnosis resulted from multidisciplinary discussion in only 50% of cases . It is noteworthy that in the current study, 43% of completing physicians stated that in most cases of suspected IPF, they made the diagnosis by themselves with the aid of diagnostic guidelines. We demonstrate that weekly MDT meeting attendance among experienced non-university hospital physicians increased prognostic accuracy of IPF diagnosis to that achieved by IPF experts.
Our findings may have implications for future multidisciplinary practice. Based on several studies of diagnostic agreement and accuracy over the past decade, MDT evaluation of IPF has become enshrined in the literature as the optimum approach to diagnostic synthesis [1, 12, 13, 15, 20, 23, 24]. A difficulty implementing this recommendation is that local access to multidisciplinary expertise may be limited. One possible solution to this problem is to network with academic centres using different forms of telemedicine. Since the web-based evaluation of patients in this study to some extent replicates telemedicine methodologies, our findings provide support for telemedicine as an acceptable form of multidisciplinary practice [24, 25]. Such collaboration could also include guidance on setting up local community hospital MDT meetings or having community physicians attend MDT meetings at local university hospitals.
Our study has some unavoidable limitations, common to previous studies of multidisciplinary practice [15–17]. First, unlike real-world clinical practice, it was impractical for physicians to engage in face-to-face consultation with patients, meaning that doctors did not have the chance to take a clinical history or examine the patients themselves. In complex disease, direct contact with the patient may influence a clinician's impression in a manner that is not easy to quantify objectively. However, direct patient contact in a study of this size would have been impracticable. Our methodology of web-based case reviews is instead similar to that of previously published studies of diagnostic agreement and accuracy between MDT meetings [15, 20, 26]. Second, physicians who completed the study were more likely to be fellowship trained, work at university institutions, attend MDT meetings and diagnose more cases of IPF per month. Nevertheless, sufficient numbers of physicians working in non-university institutions and without access to MDT meetings took part in our study, allowing us to perform statistically meaningful analyses in these subgroups. Third, to our knowledge no guideline recommendation indicates what precisely constitutes a valid MDT meeting. Although we asked physicians if they participated in formal MDT meetings, we did not attempt to quantify informal interspecialty consultation, which might also be considered by some to be a form of multidisciplinary practice . An investigation to identify the optimum MDT meeting format could be the focus of future investigations. Fourth, although poor outcome separates IPF from other ILDs, the natural history of IPF is heterogeneous and therefore there is likely to be some overlap between the two disease groupings (IPF versus not IPF). Finally, although our selection of cases from 2010 meant that mortality differences between patients with IPF and other ILDs were not confounded by treatment with antifibrotic therapy, we did not evaluate the potential confounding influences of immunosuppressive therapy (which may be harmful in IPF patients) on mortality.
In conclusion, our study indicates that diagnostic agreement for IPF is acceptable among a large group of respiratory physicians of varying degrees of experience and drawn from a wide range of geographic locations. However, experienced respiratory doctors who work at university-based institutions show greater agreement on a diagnosis of IPF and make greater prognostic distinctions between IPF and other diffuse lung diseases than those at non-university institutions. Importantly, the diagnostic performance of experienced non-university practitioners improves with regular MDT meetings. These results may be a stimulus for greater interaction between university and community hospitals as well as the development of local MDT meetings for the specific purpose of assessing patients with suspected IPF.
Please note: supplementary material is not edited by the Editorial Office, and is uploaded as it has been supplied by the author.
Supplementary material ERJ-00936-2017_Supplement
J. Behr ERJ-00936-2017_Behr
K. Brown ERJ-00936-2017_Brown
V. Cottin ERJ-00936-2017_Cottin
B. Crestani ERJ-00936-2017_Crestani
K. Flaherty ERJ-00936-2017_Flaherty
I. Glaspole ERJ-00936-2017_Glaspole
D. Hansell ERJ-00936-2017_Hansell
K. Johannson ERJ-00936-2017_Johannson
M. Kolb ERJ-00936-2017_Kolb
Y. Kondoh ERJ-00936-2017_Kondoh
M. Kreuter ERJ-00936-2017_Kreuter
T. Maher ERJ-00936-2017_Maher
F. Martinez ERJ-00936-2017_Martinez
H. Nunes ERJ-00936-2017_Nunes
G. Raghu ERJ-00936-2017_Raghu
L. Richeldi ERJ-00936-2017_Richeldi
C. Ryerson ERJ-00936-2017_Ryerson
P. Spagnolo ERJ-00936-2017_Spagnolo
S. Tomassetti ERJ-00936-2017_Tomassetti
D. Valeyre ERJ-00936-2017_Valeyre
C. Vancheri ERJ-00936-2017_Vancheri
S. Walsh ERJ-00936-2017_Walsh
M. Wijsenbeek ERJ-00936-2017_Wijsenbeek
W. Wuyts ERJ-00936-2017_Wuyts
Members of the IPF Project Consortium are as follows: Ping Shi Zhu, Yiming Yuan, Cesar Yoshito Fukuda, Yuki Yoshimatsu, Antoni Xaubet, Ai Ming Wong, Peter White, Gloria Westney, Alex West, Thomas Wessendorf, Yuko Waseda, Chingyu Wang, Jose Maria Vienna, Jelica Videnovic Ivanov, Vanesa Vicens Zygmunt, Maria Del Carmen Venero Caceres, Gerson Velásquez Pinto, Elizabeth Veitch, Martina Vasakova, Francesco Varone, Brenda Elena Varela, Peter Van Hal, Marjo Van De Ven, Ivo Van Der Lee, Leon Van Den Toorn, Amaia Urrutia Gajate, Ján Urban, Luis Gonzalo Ugarte Fornell, Argyrios Tzouvelekis, Kevin Twohig, Alice Turner, Sergio Trujillo, Antonio Triani, Daniel Traila, Veronica Torres, Hiromi Tomioka, Keisuke Tomii, Rade Tomic, Claudia Toma, Fatma Tokgoz Akyil, Kazunori Tobino, Ricardo Tobar, Anupama Tiwari, Regina Tibana, Xinlun Tian, Muhunthan Thillai, Weiping Tham, Felicia Teo, Jasna Tekavec Trkanjec, Paulo Teixeira, David Tarpey, Leonidas Tapias, Kiminobu Tanizawa, Yoshinori Tanino, Toshinori Takada, Gabriela Tabaj, Erzsebet Szolnoki, Rajesh Swarnakar, Irina Strambu, Martina Sterclova, Katherine Spinks, Chun Ian Soo, Amir Soltani, Sonam Solanki, Eman Sobh, Maria Raquel Soares, Jan Smith, Brian Smith, Philip Slocum, Hans Slabbynck, Ilya Sivokozov, Adrian Shifren, Shih Min Shen, Charles Sharp, Aruna Shanmuganathan, Alfredo Sebastiani, Simone Scarlata, Recep Savas, Shinichi Sasaki, Joanna Santeliz, Alfredo N.C. Santana, Rafaela Sanchez, Mauricio Salinas, Shigeki Saito, Frank Ryan, Juan Antonio Royo Prats, Elisabetta Rosi, Haala Rokadia, Alejandro Robles Perez, Pilar Rivera Ortega, Maite Rio Ramirez, Stefano Righetti, Cristina Reichner, Claudia Ravaglia, Pailin Ratanawatkul, Vijaya Ramalingam, Arvind Rajasekaran, Elzbieta Radzikowska, Seung Won Ra, Silvia Quadrelli, Juan Precerutti, Jyotika Prasad, Daniel Popa, Silvia Pizzolato, Wojciech Piotrowski, Andres Pineiro, Davide Piloni, Tatjana Peroš Golubičić, Rafael Perez, Carlos Pereira, Brett Pereira, Michael Perch, Nina Patel, Dharmesh Patel, Ilias Papanikolaou, Despina Papakosta, Efstratios Panselinas, Yong Kek Pang, Priyada Pandya, Eva Padrão, Ozlem Ozdemir Kumbasar, Maria J. Overbeek, Armine Otto Minasian, Deirdre O'Riordan, Josuel Ora, Justin Oldham, Oguzhan Okutan, Shinichiro Ohshimo, I.Kivilcim Oguzulgen, Takashi Ogura, Timothy O'Donnell, Conor O'Dochartaigh, Sarah O'Beirne, Mario Nunes, Lubov Novikova, Luca Novelli, Imre Noth, Nilson Nogueira Mendes Neto, Mitra Niroumand, Asunción Nieto, Alexandra Neves, Anoop Nambiar, Sudhir Nair, Rufai Nadama, Eoin Murtagh, Marco Mura, Joachim Müller Quernheim, Ansuman Mukhopadhyay, Suranjan Mukherjee, Julie Morisset, Onofre Moran, Joshua Mooney, Janne Møller, Nesrin Mogulkoc, Atsushi Miyamoto, Branislava Milenkovic, Stephen Mette, Mayra Mejia, Federico Mei, Mariano Mazzei, Toshiaki Matsuda, Carol Mason, Manuela Martínez Francés, George Margaritopoulos, Silvina Mannarino, Eliane Mancuzo, Foteini Malli, Puneet Malhotra, Martin Maillo, Jose Maia, Masoud Mahdavian, Flemming Madsen, Tracy Luckhardt, William Lucht, Su Ying Low, Concepcion Patricia Lopez Miguel, Randolph Lipchik, Steven Levy, Kovi Levin, Kai Ling Lee, David Lederer, Matthew Lammi, Hoi Yee Kwan, Sandeep Kukreja, Anuk Kruavit, Vasilis Kouranos, Mateusz Kotecki, Likurgos Kolilekas, Maria Kokosi, Heiko Knoop, Esen Kiyan, Tomoo Kishaba, Melissa King Biggs, Yet H Khor, Ayaz Khan, Nasreen Khalil, Ravindra Kedia, Naomi Kebba, Leticia Kawano Dourado, Kent Kapitan, Chung Dann Kan, Ali Fuat Kalyoncu, Meena Kalluri, Yasemin Kabasakal, Soma Jyothula, Maria Antonia Juretschke, Eoin Judge, Dragana Jovanovic, René Jonkers, Helen Jo, Shinyu Izumi, Haruyuki Ishii, Satoshi Ikeda, Aishah Ibrahim, Abdalla Ibrahim, Arfian Ibrahim, Charlotte Hyldgaard, Gary Hunninghake, Tristan Huie, Alison Hufton, Xiaowen Hu, Wan Chin Hsieh, Rodrigo Hoyos, Rachel Hoyles, Omar Holguin Rodriguez, Marie Pier Hogan, Ulla Hodgson, Helen Hilkin Sogoloff, Edwin Herrera, Brandon Michael Henry, Merel Hellemons, Ana Hecimovic, Ryuji Hayashi, Simon Hart, Sergio Harari, Sarah Haney, Nathan Hambly, Rismon Hakkim, Mónica Gutiérrez, Ria Gripaldo, Alejandro Gomez, Nicole Goh, Raul Godoy, Christopher Gilbert, Ioannis Giannarakis, Stefano Gasparini, Puneet Garcha, Sofia Furtado, Alessandro Fois, Patrick Flood Page, Sophie Fletcher, Elie Fiss, Juan Figueroa Casas, Marcelo Figueroa Casas, Christine A. Fiddler, Giovanni Ferrara, Marcelo Fernandez Casares, Charles Felton, Paola Faverio, Alexandre Todorovic Fabro, Andrea Estrada, Peter Errhalt, Noriyuki Enomoto, Juan Ignacio Enghelmayer, Karim El Kersh, Glenn Eiger, Anna Dubaniewicz, Fotios Drakopanagiotakis, Supparerk Disayabutr, Antoon Dijkstra, Juan Carlos Diaz Patiño, Jesus Javier Diaz Castañon, Sahajal Dhooria, Devesh J Dhasmana, Marino De Rosa , Stefano De Luca, Alain Delobbe, Diemen Delgado, Cesar Delgado, Isabel De La Fuente, Martijn De Kruif, Martin De Gier, Joao De Andrade, Jesper Rømhild Davidsen, Baseem Daoud, Klaus Dalhoff, Juan Vicente Cotera Solano, Andre Nathan Costa, Soledad Coronel, Marco Confalonieri, Lennart Conemans, Alejandro Comellas, Sara Colella, Susana Clemente, John Clark, Marcello Ciuffreda, Chi Li Chung, Sy Giin Chong, Daniela Chirita, Po Lin Chen, Nazia Chaudhuri, Daniel Chambers, George Chalmers, Dennis Chairman, Gin Tsen Chai, Ronald Chacon Chaves, Veli Çetinsu, Michele Ceruti, Cecilio Omar Ceballos Zuñiga, Diego Castillo, Roberto G Carbone, Antonella Caminati, Francisco Javier Callejas González, Marcus Butler, Cesar Bustos, Marcin Bukowczan, Ivette Buendia, Giuseppe Brunetti, Angel Brown, Ben Brockway, Paul Bresser, José Breseghello, Demosthenes Bouros, Juan Antonio Botero Zaccour, Gisella Borzone, Raphael Borie, Hans Christian Blum, Jacky Blank, Abhishek Biswas, David Bennett, Mark Benjamin, Ionela Nicoleta Belaconi, Paul Beirne, Lutz Beckert, Shalini Bastiampillai, Rebecca Bascom, Brian Bartholmai, Manuel Barros, Andrea Yu Lin Ban, Elisabetta Balestro, Bruno Baldi, José Baddini Martinez, Archana Baburao, Suresh Babu, Alexander Averyanov, Sergey Avdeev, Rodrigo Athanazio, Ersan Atahan, Bassey Asuquo, Deborah Assayag, Julio Antuni, Sofia Antillon, Kenneth C Anderson, Adam Anderson, Fida Alwani, Goksel Altinisik, Neamat Alsouofi, J. Shirine Allam, Hamdan Al Jahdali, Abdulla Al Farttoosi, Tiago Alfaro, Nasser Al Busaidi, Ali Alavi Foumani, Maria Gloria Agreda Vedia, Amit Agarwal, Faraz Afridi, Olufunke Olayinka Adeyeye, Ayodeji Adegunsoye, Huzaifa Adamali, Atefeh Abedini.