Abstract
We study how the optimal degree of conservatism relates to decision-making procedures in a Monetary Policy Committee (MPC). In our framework, central bank conservatism is required to attenuate the volatility of monetary decisions generated by the presence of uncertainty about the committee members’ output objective. We show how this need for conservatism varies according to the number of MPC members, the MPC’s composition as well as its decision rule. Moreover, we find that extra central bank conservatism is required when there is ambiguity about the MPC’s true decision rule.
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Notes
For a typology of the different aspects of central bank transparency, see Geraats (2002).
A series of papers has used the “robust control” approach initiated by Hansen and Sargent (2005, 2008) to determine optimal monetary policy when the central bank faces some uncertainty. For recent contributions to the robust control literature in general, see for instance Tillmann (2009a) or Tillmann (2014). However, closer to our analysis are the papers by Tillmann (2009b) and Sorge (2013) where the “robust control” approach is adapted to determine the optimal degree of conservatism when the social planner faces some uncertainty, respectively, about cost-push shock persistence and central bank preferences.
Hayo and Mazhar (2014) study the determinants of the degree of MPC transparency. They find that past inflation and the quality of institutional set up significantly influence MPC transparency.
Gersbach and Hahn (2009) argue that the ECB has been right to do so as this opacity helps to protect its committee from national politicians’ interferences.
We assume that the preference shocks \({\epsilon _{t}^{i}}\) are independent of the cost-push shock e t , so that \(E_{t}\left (\epsilon _{t}^{i}e_{t}\right ) =0\). We also assume that there is no systematic relation between λ i and 𝜖 i . That is, the social planner can not set λ C B so as to reduce the influence of 𝜖 i.
We could also assume that uncertainty concerns the weights the central bank attaches to its policy objectives, as for example in Hefeker and Zimmer (2011a). This would render our model less tractable without fundamentally changing the results.
Orphanides and van Norden (2002) show that estimation errors of the output gap are highly persistent over time. In our analysis, however, the policymakers’ preference shock \({\epsilon _{t}^{i}}\) is i.i.d. and thus transitory. For studies where this shock has a persistent component, see Faust and Svensson (2001, 2002) or Westelius (2009).
Obviously, n b +n e x t =n so that the MPC is formed by n+1 members.
Parameter q can also be seen as a binary number where a value of 1 (0) implies that council members resort to averaging (majority voting). Another interpretation of q would be that it represents the probability that the council reaches a consensus; (1−q) being the probability that the council fails to reach a consensus, in which case it has to resort to voting. Obviously, with both interpretations of q, no distinction is made between board and external members within the council so that n b =n e x t =n and \( {\epsilon _{t}^{b}}=\epsilon _{t}^{ext}\).
Studying the properties of this function, we observe that: \(\frac {\partial f(\lambda _{CB})}{\partial \lambda _{CB}}=\frac { 3\alpha ^{2}\beta \rho \left (\lambda _{G}\alpha ^{2}+1\right ) \left (1-\rho ^{2}\right ) \left (\alpha ^{2}\lambda ^{CB}+1-\beta \rho \right )^{2}V\left ({\epsilon _{t}^{j}}\right )}{\left (1-\beta \rho \right ) \left (\alpha ^{2}\lambda _{CB}+1\right )^{4}}>0\). Hence, f(λ C B ) is monotonically increasing in λ C B . Moreover, \(\frac {\partial ^{2}f(\lambda _{CB})}{\partial ^{2}\lambda _{CB}}=\frac {-6\alpha ^{4}\beta \rho \left (\lambda _{G}\alpha ^{2}+1\right ) \left (1-\rho ^{2}\right ) \left (\alpha ^{2}\lambda ^{CB}+1-\beta \rho \right ) \left (\alpha ^{2}\lambda ^{CB}+1-2\beta \rho \right ) V\left ({\epsilon _{t}^{j}}\right )}{\left (1-\beta \rho \right ) \left (\alpha ^{2}\lambda _{CB}+1\right )^{5}}\) becomes negative – implying that f(λ C B ) is concave – for sufficiently low values of β and ρ and/or sufficiently large values of λ C B and α.
This result implies that the optimal size of the committee is infinite. Incorporating additional effects like efficiency or decision costs would obviously restrict the optimal committee size (Berger 2006). This issue, however, is beyond the scope of our paper.
By contrast with the uncertainty about preferences where the social planner perfectly knows the mean and the variance of 𝜖 – otherwise he would not be able to select the policymakers –, when considering the case of uncertainty about the MPC’s decision structure, we suppose that the social planner is unable to assign any probability measure to this randomness. This can be justified by the fact that he has no possibility to influence the MPC’s decision-making choice and thereby considers the worst possible scenario.
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Acknowledgments
For helpful comments, we thank two anonymous referees, Ansgar Belke, Lawrence Broz, Sylvester Eijffinger, Etienne Farvaque, Volker Hahn, Nikolaj Harmon, Ummad Mazhar, Pierre-Guillaume Méon, Cornel Oros and Peter Tillmann as well as participants to presentations in Duisburg, Leipzig, Münster, Poitiers, Strasbourg, at the 16th International Conference on Macroeconomic Analysis and International Finance in Rethymno, the 16th T2M Conference in Nantes, the 61st annual meeting of AFSE in Paris, the 2013 Meeting of the European Public Choice Society in Zurich, the INFER Annual Conference 2013 in Orléans, the 13th annual conference of the Viessmann Research Center in Waterloo, and at Ifo-Institute in Munich.
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Appendix
Appendix
Proof of Result 1
From expression (15), it is easy to see that \(\frac {\partial f}{ \partial V\left ({\epsilon _{t}^{j}}\right )}>0\). Hence, a rise in \(V\left ({\epsilon _{t}^{j}}\right )\) causes an upward shift of the function f and thereby a shift to the right of the intersection point between the 45∘ line and the function f curve, implying an increase in λ C B∗.
As \(\epsilon _{t}^{AR}={{\sum }_{i}^{n}}{\epsilon _{t}^{i}}/n\), the aggregation process implies: \(E\left (\epsilon _{t}^{AR}\right )=0\) and \(V\left (\epsilon _{t}^{AR}\right )=\sigma _{\epsilon }^{2}/n\). Further, since \(\epsilon _{t}^{MR}=\text {median} \left [{\epsilon _{t}^{1}},...,{\epsilon _{t}^{n}}\right ]\), we have \(E\left (\epsilon _{t}^{MR}\right )=0\) and \(V\left (\epsilon _{t}^{MR}\right )=\frac {\Pi }{2n}\sigma _{\epsilon }^{2}\).Footnote 18
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i)
It is obvious from Eq. 15 that λ C B∗ > λ G even if ρ = 0.
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ii)
Since \(V\left (\epsilon _{t}^{CBi}\right )=\sigma _{\epsilon }^{2}\) , it follows that \(V\left (\epsilon _{t}^{CBi}\right )>V\left (\epsilon _{t}^{MR}\right )\) and \( V\left (\epsilon _{t}^{CBi}\right )>V\left (\epsilon _{t}^{AR}\right )\). Consequently, \(\lambda _{CB\ast }^{CBi}>\lambda _{CB\ast }^{MR}\) and \(\lambda _{CB\ast }^{CBi}>\lambda _{CB\ast }^{AR}\).
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iii)
Since \(\frac {\partial V\left (\epsilon _{t}^{AR}\right )}{ \partial n}<0\) and \(\frac {\partial V\left (\epsilon _{t}^{MR}\right )}{\partial n}<0\), \( \lambda _{CB\ast }^{AR}\) and \(\lambda _{CB\ast }^{MR}\) depend negatively on n.
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iv)
Finally, as \(V\left (\epsilon _{t}^{AR}\right )<V\left (\epsilon _{t}^{MR}\right )\) we have \(\lambda _{CB\ast }^{AR}<\lambda _{CB\ast }^{MR}\), according to the graphical analysis.
□
Proof of Result 2
To demonstrate result 2, we begin by deriving \(V\left (\epsilon _{t}^{GEN}\right )\):
Differentiating this expression with respect to p yields:
This derivative is negative if \(p<\frac {q^{2}\frac {{\sigma _{b}^{2}}}{n_{b}} +(1-q)^{2}\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}}{\sigma _{chair}^{2}+q^{2} \frac {{\sigma _{b}^{2}}}{n_{b}}+(1-q)^{2}\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}} }=p_{\min }\) and becomes positive otherwise. Hence, \(p_{\min }\) minimises \( V\left (\epsilon _{t}^{GEN}\right )\) and the optimal degree of conservatism \(\lambda _{CB\ast }^{GEN}\) as well.
We then turn to the council and differentiate \(V\left (\epsilon _{t}^{GEN}\right )\) with respect to q. In doing this, we obtain:
This derivative is negative for \(q<q_{\min }=\frac {\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}}{\frac {{\sigma _{b}^{2}}}{n_{b}}+\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}}\) and positive otherwise. As a consequence, \(q_{\min }\) minimises \(V\left (\epsilon _{t}^{GEN}\right )\) and thereby the optimal degree of conservatism \(\lambda _{CB\ast }^{GEN}\). □
Proof of Result 3
To solve problem (16), the first stage is to identify the realizations of (p UN,q UN) that maximise the expected social loss:
Note that \(E\left [{L_{t}^{G}}\left (\epsilon _{t}^{UN}\right )\right ]\) only depends on p UN and q UN via \(E\left (\epsilon _{t}^{UN}\right )^{2}\). The social planner first determines the allocation of decision power within the council that maximises the expected social loss. Differentiating \(E\left (\epsilon _{t}^{UN}\right )^{2}\) with respect to q UN yields
As has already been demonstrated, for a given p, \(E\left (\epsilon _{t}^{UN}\right )^{2} \) attains its minimum for \(q_{min}=\frac {\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}}{\frac {{\sigma _{b}^{2}}}{n_{b}}+\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}}\) and thus its maximum for extreme values of q in the interval [0,1]. We finally compare \(E\left (\epsilon _{t}^{UN}|_{q=0}\right )^{2}= \frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}\) with \(E\left (\epsilon _{t}^{UN}|_{q=1}\right )^{2}=\frac {{\sigma _{b}^{2}}}{n_{b}}\) to show that if \(\frac { {\Pi } \sigma _{ext}^{2}}{2n_{ext}}>(<)\frac {{\sigma _{b}^{2}}}{n_{b}}\), q m a x – i.e. the value of q that maximises \(E\left (\epsilon _{t}^{UN}\right )^{2}\) and thus \(E\left [{L_{t}^{G}}\left (\epsilon _{t}^{UN}\right )\right ]\) – is equal to 0 (1).
Once q m a x has been determined, the social planner turns to p m a x , the value of p that maximises \(E\left (\epsilon _{t}^{UN}\right )^{2}\) and thus \( E\left [{L_{t}^{G}}\left (\epsilon _{t}^{UN}\right )\right ]\).
Taking the derivative of \(E\left (\epsilon _{t}^{UN}\right )^{2}\) with respect to p UN yields
For a given q=q m a x , \(E\left (\epsilon _{t}^{UN}\right )^{2}\) has its minimum at \( p_{min}=\frac {q^{2}\frac {{\sigma _{b}^{2}}}{n_{b}}+(1-q)^{2}\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}}{\sigma _{chair}^{2}+q^{2}\frac {{\sigma _{b}^{2}}}{n_{b}} +(1-q)^{2}\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}}\) and its maximum for extreme values of p in the interval [0,1]. We thus compare \(E\left (\epsilon _{t}^{UN}|_{p=0}\right )^{2}=\left (q_{max}\right )^{2}\frac {{\sigma _{b}^{2}}}{n_{b}} +(1-q_{max})^{2}\frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}\) with \(E\left (\epsilon _{t}^{UN}|_{p=1}\right )^{2}=\sigma _{chair}^{2}\).
If \(\left (q_{max}\right )^{2}\frac {{\sigma _{b}^{2}}}{n_{b}}+(1-q_{max})^{2} \frac {\Pi \sigma _{ext}^{2}}{2n_{ext}}>\sigma _{chair}^{2}\), then p m a x =0 , otherwise p m a x =1. In both cases, \(E\left (\epsilon _{t}^{UN}\right )^{2}=V\left (\epsilon _{t}^{UN}\right )>V\left (\epsilon _{t}^{GEN}\right )\) – the latter being defined by Eq. 19 – which means that the optimal degree of conservatism, \(\lambda _{CB\ast }^{UN}\), when the MPC’s decision procedure is unknown is higher than \(\lambda _{CB\ast }^{GEN}\), the one obtained under transparency about the decision procedure. □
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Hefeker, C., Zimmer, B. Optimal Conservatism and Collective Monetary Policymaking under Uncertainty. Open Econ Rev 26, 259–278 (2015). https://doi.org/10.1007/s11079-014-9329-5
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DOI: https://doi.org/10.1007/s11079-014-9329-5