bank interconnectedness what determines the links? - puriya abbassi, christian brownlees, christina...
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Bank Interconnectedness What determines the links? - Puriya Abbassi, Christian Brownlees, Christina Hans, Natalia Podlich. SYRTO Code Workshop Workshop on Systemic Risk Policy Issues for SYRTO (Bundesbank-ECB-ESRB) Head Office of Deustche Bundesbank, Guest House Frankfurt am Main - July, 2 2014TRANSCRIPT
Bank Interconnectedness
What determines the
links?
SYstemic Risk TOmography:
Signals, Measurements, Transmission Channels, and Policy Interventions
Puriya Abbassi, Natalia Podlich Deutsche Bundesbank Christian Brownlees, Christina Hans Universitat Pompeu Fabra SYRTO Code Workshop Workshop on Systemic Risk Policy Issues for SYRTO July, 2 2014 - Frankfurt (Bundesbank-ECB-ESRB)
Introduction Data Model Estimation Empirical Results Conclusion
Bank Interconnectedness
What determines the links?
Puriya Abbassi† Christian Brownlees‡
Christina Hans‡ Natalia Podlich†
† Deutsche Bundesbank
‡Universitat Pompeu Fabra
02.07.2014
Introduction Data Model Estimation Empirical Results Conclusion
Motivation
• Modelling network structures has become increasinglyimportant both for researchers and for policy makers toassess the potential of contagion in the financial system
• Which network configuration is more dangerous for thefinancial system?
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Introduction Data Model Estimation Empirical Results Conclusion
Motivation
• Modelling network structures has become increasinglyimportant both for researchers and for policy makers toassess the potential of contagion in the financial system
Quarter 4, 2006 Quarter 4, 2007 Quarter 4, 2008
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Introduction Data Model Estimation Empirical Results Conclusion
Motivation
• Approaches to compute interconnectedness from marketdata are widely used in order to assess financial stabilityand systemic default probability
• But: what is the relation between perceived connectivityimplied by the market and fundamental channels?
• Data on networks through e.g. interbank lending orasset commonality is confidential or not available
• The information reflected by networks based on publiclyavailable data is unclear
Introduction Data Model Estimation Empirical Results Conclusion
Motivation
• Efficient market hypothesis: financial markets areinformationally efficient, and prices contain all availableinformation
• Question: What is the information content of networkscomputed using market data? Do they reflect
• Direct connections through bilateral exposures• Indirect connections through commonalities• Information contagion
...or not fundamentally driven market expectations?
Introduction Data Model Estimation Empirical Results Conclusion
Idea of this work
• Central questions:• What is the relation between networks based on publicly
available data and fundamental channels ofinterconnectedness?
• What is the information content of the time-varyingcomponent?
Introduction Data Model Estimation Empirical Results Conclusion
Idea of this work
• Our approach:• Model network structures for a sample of German banks
based on CDS data
• Compare their information content to two fundamentalchannels:
• Direct connections through interbank exposures
• Indirect connections through common exposures tosimilar asset classes
Introduction Data Model Estimation Empirical Results Conclusion
Roadmap
1. Overview of related literature
2. Data used in this study
3. Preliminary empirical findings
4. The way forward
Introduction Data Model Estimation Empirical Results Conclusion
Related literature
1. Networks based on market data• Billio, Getmansky, Lo & Pelizzon 2011 JFE - Granger Causality
Networks to determine structure of the financial system based on equityreturns
• Brownlees, Nualart & Hans 2014 WP - Credit Risk networkderived from idiosyncratic default intensities of banks based on CDS data
2. Interbank Lending Networks• Allen & Gale 2000 JPE - Theoretical model on financial contagion
through interbank markets• Iyer & Peydro 2009 - Empirical evidence for contagion through
interbank markets at the example of India
3. Interconnections through Asset Commonality• Allen, Babus & Carletti 2011 JFE - Theoretical model on
contagion effects through asset commonality• Caballero & Simsek 2013 JF - Theoretical model on fire sales in
complex environments
Introduction Data Model Estimation Empirical Results Conclusion
Data
• Our source for estimating credit risk networks: CDSspreads
• Bilateral swap agreements denoted in annualized basispoints
• Clean measure of credit risk of single institutions
• Total size of the CDS market in July 2007: $ 62.2 trillion
Introduction Data Model Estimation Empirical Results Conclusion
Data
• Sample of 13 large German banks
• CDS spreads of 1-year, 3-year, 5-year, 7-year and 10-yearmaturity for German sovereign and banks, daily frequency
• Riskless rate (Nelson-Siegel-Svensson curves)
• Interbank lending data from the Deutsche Bundesbankcredit register (all exposures > €1.5mio to financialfirms), quarterly frequency (confidential)
• Bank portfolio data, quarterly frequency (confidential)
• Sample period: October 1, 2005 - December 31, 2012
Descriptive Statistics
Introduction Data Model Estimation Empirical Results Conclusion
Credit Risk Model for CDS pricing
• Brownlees, Nualart & Hans 2014: Model for a panel offinancial entities building up on the standard reducedform framework for CDS pricing
• Default of single institutions can be triggered by twocomponents:
1. Systematic component (e.g. common macroeconomicshocks)
2. Idiosyncratic component with network structure (seeModel )
modelled as jumps of a Poisson process with stochasticintensity driven by a Brownian motion.
Introduction Data Model Estimation Empirical Results Conclusion
Credit Risk Model for CDS pricing
• The vector of Brownian Motions driving the idiosyncraticprocesses is allowed to have a covariance matrix
• The Bank Credit Risk Network is defined as a weighted,undirected graph, where two banks are connected iff theiridiosyncratic shocks are conditionally dependent.
• Hence, obtained linkages should reflect directbank-to-bank connections through various channels
Introduction Data Model Estimation Empirical Results Conclusion
Step 1: Estimating the Bank Credit Risk Network
1. We use a standard bootstrapping algorithm for strippingout perceived default intensities for both the sovereignand the 13 banks in our sample from CDS spreads.
2. We obtain idiosyncratic default intensities for all banks byfiltering out the systematic influence.
3. We estimate the structure of the bank credit risk networkas partial correlations among those, and use LASSO typeestimation for recovering the sparsity structure of thenetwork.
LASSO
Introduction Data Model Estimation Empirical Results Conclusion
Step 2: Judging the determinants
We take the bank credit risk network estimated on a quarterlybasis and assess the impact of both direct and indirectchannels of interconnectedness by estimating
ρijt = β0 + β1Iijt + β2Dijt + β3Cijt−1 + αt + γij + εijt
where
• ρijt is the partial correlation according to our model
• Iijt denotes the interbank exposure
• Dijt is a measure of portfolio distance
• Cijt−1 is a set of back-dated pair-wise control variables
between banks i and j at time t.
Introduction Data Model Estimation Empirical Results Conclusion
Preliminary Results
• Roughly 15 % of the variation in the partial correlationnetwork can be attributed to bank-pair information
• Approach to capture bank-to-bank component:• Interbank exposures• Common risk exposures
Introduction Data Model Estimation Empirical Results Conclusion
Preliminary Results
Interbank Exposures:
• Low explanatory power per se, in line with previousliterature: if interbank lending network is complete, it isrobust to shocks (Allen & Gale 2000)
• Interbank exposures relative to a bank’s Core Tier 1Capital: the higher interbank exposures with respect tocapital, the higher the partial correlations
• The effect is non-linear and stronger when the lossabsorption capacity is small
Introduction Data Model Estimation Empirical Results Conclusion
Preliminary Results
Common Risk Exposures:
• Portfolio similarity of two banks (Cai, Saunders & Steffen2014):
Dijt =
√√√√ A∑a=1
(wiat − wjat)2
where wiat is the relative portfolio weight along threedimensions
• Weak overall significance
• Stronger effects if we focus on troubled asset classes
Introduction Data Model Estimation Empirical Results Conclusion
Preliminary Results
What about the remaining 85 %?
• Relationships through fundamental channels are generallymore persistent and rigid over time relative to CDS pricedevelopments
• Amplification mechanism might differ across and withinthe financial and sovereign crisis
• Market expectations might not be fundamentally driven(market sentiment, ’too big to fail’)
Introduction Data Model Estimation Empirical Results Conclusion
Concluding remarks / The way forward
• We build up on a model estimating credit riskconnections in a panel of financial entities based on CDSdata, and compare its outcomes to two fundamentalchannels: interbank exposures and asset commonality
• We find that the information content of networksobtained with market data reflects both direct andindirect channels of interconnectedness, but there is alarge share left to be explained
• Next steps:• Increase sample of banks and richness of datasets• Use various ways to account for direct and indirect
channels (e.g. dependence on wholesale funding)• ...
Appendix A Appendix B Appendix C
List of banks in the sample
Category Name of the institution Abbreviation
Privatbanken Deutsche Bank AG DBACommerzbank AG COMUnicredit AG UNI
Landesbanken DekaBank Deutsche Girozentrale DGZHSH Nordbank HSHLandesbank Baden-Wurttemberg LBWBayerische Landesbank BLBLandesbank Berlin LBBLandesbank Hessen - Thuhringen LHTNorddeutsche Landesbank NLBWest LB / Portigon AG WLB
Genossenschaftsbanken DZ Bank DZBWGZ Bank AG WGZ
Appendix A Appendix B Appendix C
Quantile statistics for 5-year bank CDS spreads
Mean Std. Dev. Min. Median Max.DGZ 66.77 42.42 5.93 69.27 192.08LBW 100.81 72.15 5.62 103.5 346.07BLB 104.84 84.5 7.97 84.54 364.12LBB 89.36 59.55 8.92 92.51 317.8HSH 89.91 49.04 10.25 103.31 189.63LHT 69.97 41.72 7.92 69.9 155.8NLB 154.29 104.35 7 167.16 445.19WLB 102.79 64.47 7.29 119.19 259.97DZB 120.65 87.98 5.69 112.95 361.54WGZ 101.39 71.38 5.91 113.06 355.33DBA 103.21 69.45 5.95 116.33 302.56COM 48.55 26.04 5.63 50.93 125.64UNI 99.38 68.91 5.77 109.97 334.66
back to Data
Appendix A Appendix B Appendix C
Tibshirani 1996: LASSO
• Regression representation:
Bi(t) =∑j 6=i
βijBj(t) + ui(t)
with ui(t) ∼ N (0, tkii
) and βij = ρij√
kjjkii
• Estimate parameters as well as select and estimate thepartial correlations by minizing the following objectivefunction
ρ = minρij
∑i
∑t
[sit − sit ]2 + θ
∑j 6=i
|ρij |
based on pre–estimators of kii i = 1, ..., n
back to Model
Appendix A Appendix B Appendix C
Credit Risk Model for CDS pricing
• We develop a model for a panel of n financial entities,where default of single institutions can be triggered by
1. Systematic component
2. Idiosyncratic component
• We use the model to derive closed form CDS prices
Appendix A Appendix B Appendix C
Systematic component
• We model systematic shocks as jumps of a Poissonprocess M(t) with intensity λ
dλ(t) = a(m − λ(t))dt + b√λ(t)dW (t)
where W (t) is a Brownian motion
• Each of the i = 1, ..., n entities has a conditional defaultprobability γi following a systematic shock
Appendix A Appendix B Appendix C
Idiosyncratic component
• We model an idiosyncratic shock as the first jump ofPoisson process Ni(t) with intensity ξi
dξi(t) = αi(µi − ξi(t))dt +√ξi(t)dBi(t)
where Bi(t) are Brownian motions independent of W (t)
• We assume that B(t) = (B1(t), ...,Bn(t)) is a correlatedBrownian motion with covariance matrix Σ, where weconstrain Σ to allow for a network structure among theBi ’s
Appendix A Appendix B Appendix C
Bank Credit Risk Network
• We define the network of bank interconnections as anundirected graph N = (V , E) where V = 1, ..., n is the setof banks and E ⊂ V × V is the set of edges
• We define two banks to be connected by an edge iff theiridiosyncratic default shocks are conditionally dependent,i.e.
∀(i , j) ∈ E Bi(t) 6⊥ Bj(t) | Bk(t) ∀k 6= i , j
Appendix A Appendix B Appendix C
Bank Credit Risk Network
• We can equivalently characterize the network betweenidiosyncratic default shocks using the concentrationmatrix K = Σ−1 with entries kij
• Then two banks are conditionally independent iff kij = 0
Bi(t) ⊥ Bj(t) | Bk(t) ∀k 6= i , j ⇔ kij = 0,
in other words, E = {(i , j) : kij 6= 0}
• Important implication: We can reformulate the problemof estimating the Bank Credit Risk Network as theproblem of estimating a sparse concentration matrix
Appendix A Appendix B Appendix C
Instantaneous probability of default
Bank default probability:
P (no default occurs by time t)
= P(Ni (t) = 0)∞∑j=0
P(M(t) = j)(1− γi )j
= exp
(−∫ t
0ξi (s)ds
) ∞∑j=0
1
j!exp(−
∫ t
0λ(s)ds)
((1− γi )
∫ t
0λ(s)ds
)j
= exp
(−∫ t
0(γiλ(s) + ξi (s))ds
)
Appendix A Appendix B Appendix C
Pricing CDS
Standard framework for valuing credit derivatives(Duffie & Singleton 1999)
Protection leg of a CDS contract:
CDSpi ro = EQ
(∫ T
0
exp
[−∫ t
0
(r(s) + γiλ(s) + ξi(s))(1− ω)ds
]dt
)
Premium leg of a CDS contract:
CDSpi re = EQ
(si
∫ T
0
exp
[−∫ t
0
(r(s) + γiλ(s) + ξi(s))ds
]dt
)
Appendix A Appendix B Appendix C
Pricing CDS
For no arbitrage:CDSpro
i = CDSprei ,
hence
si =ωEQ
(∫ T
0D(t)(γiλ(s) + ξi(s)) exp
[−∫ t
0(γiλ(s) + ξi(s))ds
]dt)
EQ(∫ T
0D(t) exp
[−∫ t
0(γiλ(s) + ξi(s))ds
]dt)
=ω∫ T
0D(t)
(F i(λ(0), t)H(ξi(0), t) + γiG (ξi(0), t)I i(λ(0), t)
)dt∫ T
0(D(t)F i(λ(0), t)G (ξi(0)) dt
Appendix A Appendix B Appendix C
Closed Form Solution
F i(λ(0), t) = F1(t) exp(F2(t)λ(0))
G (ξi(0), t) = G1(t) exp(G2(t)ξi(0))
H(ξi(0), t) = (H1(t) + H2(t)ξi(0)) exp(G2(t)ξi(0))
I i(λ(0), t) = (I1(t) + I2(t)λ(0)) exp(F2(t)λ(0))
Appendix A Appendix B Appendix C
F1(t) = exp
(−am(a − ψi )t
b2
)(νi − 1
νi − etψi
) 2amb2
F2(t) =a − ψi
b2−
2ψi etψi
b2(νi − etψi )
G1(t) = exp
(−αiµi (αi − Φi )t
Γ2i
)(θi − 1
θi − etΦi
) 2αiµiΓ2i
G2(t) =α− Φi
Γ2i
−2Φi e
tΦi
Γ2i (θi − etΦi )
H1(t) =αiµi
Φi
(eΦi t − 1) exp
(−αiµi (αi − Φi )t
Γ2
)(θi − 1
θi − eΦi t
) 2αiµiΓ2i
+1
H2(t) = exp
(−αiµi (αi − Φi )t
Γ2i
+ Φi t
)(θi − 1
θi − eΦi t
) 2αiµiΓ2i
+2
Appendix A Appendix B Appendix C
I1(t) =am
ψi
(eψi t − 1) exp
(−am(a − ψi )t
b2
)(νi − 1
ν − eψi t
) 2amb2 +1
I2(t) = exp
(−am(a − ψi )t
b2+ ψi t
)(νi − 1
νi − eψi t
) 2amb2 +2
with
ψi =√
a2 + 2γi b2
νi =a + ψi
a − ψi
Φi =√α2i + 2Γ2
i
θi =αi + Φi
αi − Φi
Γ2i =
∑j 6=i,k 6=i
βijβikσjk +
1
kii
βij = ρij
√kjj
kii.
back to Model
This project has received funding from the European Union’s
Seventh Framework Programme for research, technological
development and demonstration under grant agreement n° 320270
www.syrtoproject.eu
This document reflects only the author’s views.
The European Union is not liable for any use that may be made of the information contained therein.